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Vol. CXIX August 2004 Issue 3
THE CAUSES AND CONSEQUENCES
OF DISTINCTIVELY BLACK NAMES*
ROLAND G. FRYER, JR. AND STEVEN D. LEVITT
In the 1960s Blacks and Whites chose relatively similar ?rst names for their
children. Over a short period of time in the early 1970s, that pattern changed
dramatically with most Blacks (particularly those living in racially isolated neighborhoods) adopting increasingly distinctive names, but a subset of Blacks actually
moving toward more assimilating names. The patterns in the data appear most
consistent with a model in which the rise of the Black Power movement in?uenced
how Blacks perceived their identities. Among Blacks born in the last two decades,
names provide a strong signal of socioeconomic status, which was not previously
the case. We ?nd, however, no negative relationship between having a distinctively Black name and later life outcomes after controlling for a child’s circumstances at birth.
On May 17, 1954, the landmark Supreme Court decision in
Brown v. Board of Education of Topeka, Kansas ruled, unanimously, that segregation in public schools was unconstitutional.
* We are grateful to George Akerlof, Susan Athey, Gary Becker, David Card,
John Donohue, Esther Du?o, Edward Glaeser, Shoshana Grossbard-Shechtman,
Daniel Hamermesh, Lawrence Katz, Glenn Loury, Douglas McAdam, Andrei
Shleifer, and Steven Tadelis for helpful comments and suggestions. We thank
seminar participants too numerous to mention for their comments and suggestions. We also thank two editors and three anonymous referees for detailed
feedback that improved the paper. Michael Roh provided excellent research assistance. Financial support was provided by the National Science Foundation.
A portion of this paper was written while Fryer was an NSF Post-Doctoral
Fellow at the University of Chicago and Levitt was a fellow at the Center for
Advanced Study in the Behavioral Sciences in Stanford. Correspondence can
be addressed to Fryer at Harvard University, Littauer Center, Cambridge MA
02138 (e-mail: firstname.lastname@example.org); or Levitt at Department of Economics,
University of Chicago, 1126 East 59th Street, Chicago, IL 60637 (e-mail:
© 2004 by the President and Fellows of Harvard College and the Massachusetts Institute of
The Quarterly Journal of Economics, August 2004
767This ruling paved the way for the fall of Jim Crow and large-scale
desegregation. In the 1960s a series of further government actions were taken with the goal of achieving racial equality and
integration, most notably the Civil Rights Act of 1964, Executive
Order 11246 in 1965, and the Fair Housing Act of 1968. The civil
rights movement arguably represents one of the most profound
social transformations in American history [Woodward 1974;
Nonetheless, an enormous racial divide persists. There are
large disparities between Blacks and Whites in the United States
on many indicators of social and economic welfare including income [Bound and Freeman 1992; Chandra 2003; Heckman,
Lyons, and Todd 2000; Smith and Welch 1989], educational
achievement [Jencks and Phillips 1998], out-of-wedlock childbearing [Ventura and Bachrach 2000], health (see Kington and
Nickens ), and criminal involvement [Reno et al. 1997]. The
degree of residential segregation by race, though lower today
than in 1970, remains high [Cutler, Glaeser, and Vigdor 1999;
Racial differences also persist, and in some cases have become even more pronounced, on a wide range of cultural dimensions including musical tastes [Waldfogel 2003], linguistic patterns [Wolfram and Thomas 2002], and consumption choices. For
instance, the cigarette brand Newport has a 75 percent market
share among Black teens, but just 12 percent among White teen
smokers; 65 percent of White teens smoke Marlboro compared
with only 8 percent of Blacks [Johnston et al. 1999]. Seinfeld, one
of the most popular sitcoms in television history among whites,
never ranked in the top 50 among Blacks. Indeed, of the top ten
shows with the highest viewership among Whites during the
1999 –2000 television season, only one show was also among the
top ten for blacks: NFL Monday Night Football (Nielsen Media
Understanding whether cultural differences are a cause of
continued economic disparity between races is a question of great
social importance. Cultural differences may be a cause of Black
economic struggle if Black culture interferes with the acquisition
of human capital or otherwise lowers the labor market productivity of Blacks (as argued in the culture of poverty paradigm in
sociology; see Hannerz , Lewis , Riessman ,
and implicitly, Anderson ). For instance, high-achieving
Black children may be ostracized by their peers for “acting white,”
potentially leading to lower investment in human capital
768 QUARTERLY JOURNAL OF ECONOMICS[Fordham and Ogbu 1986; Austen-Smith and Fryer 2003]. Speaking “Ebonics” may interfere with the ability to interact with
White coworkers and customers, or disrupt human capital acquisition more directly [Orr 1989]. On the other hand, the presence
of a Black culture may simply be the consequence of past and
current segregation and economic inequality, but play no role in
perpetuating economic disparity. If differences in tastes do not
in?uence human capital acquisition or labor market productivity,
then there is little reason to believe that such tastes will have a
causal negative economic impact on Blacks. For example, “soul
food” [Counihan and Van Esterik 1997] and traditional AfricanAmerican spirituals [Jackson 1944] can be traced to the social
conditions endured during slavery, but are unlikely to be causes
of current poverty. Eliminating cultural differences in this scenario would have no overall impact on Black welfare relative to
A primary obstacle to the study of culture has been the lack
of quantitative measures. In this paper we focus on one particular
aspect of Black culture—the distinctive choice of ?rst names—as
a way of measuring cultural investments.
Our research builds
upon a growing literature by economists devoted to understanding a diverse set of social and cultural phenomena [Akerlof and
Kranton 2000; Berman 2000; Fryer 2003; Glaeser, Laibson, and
Sacerdote 2002; Iannaccone 1992; Lazear 1999]. In contrast to
these earlier papers, however, our contribution is primarily
Using data that cover every child born in California over a
period of four decades, our analysis of ?rst names uncovers a rich
set of facts. We ?rst document the stark differences between
Black and White name choices in recent years.
more than 40 percent of the Black girls born in California in
recent years received a name that not one of the roughly 100,000
White girls born in California in that year was given.
1. Other than the audit studies of resumes discussed below, the only other
economic analysis of name choices that we are aware of is Goldin and Shim 
which examines the issue of women retaining their maiden names at marriage.
The seminal work on names outside of economics has been done in a series of
papers by Stanley Lieberson and coauthors, culminating in Lieberson .
2. There are multiple dimensions along which a name can be considered
“black” or “white.” For example, Lieberson and Mikelson  study distinctive
patterns of phonemes that are characteristic of Black names. In this paper we
study only one dimension of the issue: the relatively frequency with which Blacks
and Whites choose a given name for their children.
3. Lieberson and Mikelson , using a sample of names from birth
records in Illinois, ?nd that approximately 30 percent of black baby girls born
DISTINCTIVELY BLACK NAMES 769among popular names, racial patterns are pronounced. Names
such as DeShawn, Tyrone, Reginald, Shanice, Precious, Kiara,
and Deja are quite popular among Blacks, but virtually unheard
of for Whites.
The opposite is true for names like Connor, Cody,
Jake, Molly, Emily, Abigail, and Caitlin. Each of those names
appears in at least 2,000 cases (between 1989 –2000), with less
than 2 percent of the recipients Black.
Overall, Black choices of
?rst names today differ substantially more from Whites than do
the names chosen by native-born Hispanics and Asians.
More surprising, perhaps, is the time series pattern of Black
?rst names. In the 1960s the differences in name choices between
Blacks and Whites were relatively small, and factors that predict
distinctively Black names in later years (single mothers, racially
isolated neighborhoods, etc.) have much lower explanatory power
in the 1960s. At that time, Blacks who lived in highly racially
segregated neighborhoods adopted names that were almost indistinguishable from Blacks in more integrated neighborhoods and
similar to Whites. Within a seven-year period in the early 1970s,
however, a profound shift in naming conventions took place,
especially among Blacks in racially isolated neighborhoods. The
median Black female in a segregated area went from receiving a
name that was twice as likely to be given to Blacks as Whites to
a name that was more than twenty times as likely to be given to
Blacks. Black male names moved in the same direction, but the
shift was less pronounced. On the other hand, among a subset of
Blacks encompassing about one-fourth of Blacks overall and onehalf of those in predominantly White neighborhoods, name
choices actually became more similar to those of Whites during
this same period.
We argue that these empirical patterns are most consistent
with a model in which the rise of the Black Power movement
in?uenced Black identity. Other models we consider, such as
ignorance on the part of Black parents who unwittingly stigmabetween 1920 and 1960 have unique names. Starting in the early 1960s, there was
a remarkable increase in the prevalence of unique names, resulting in a peak in
1980 in which 60 percent of Black girls were given unique names. A similar,
though less pronounced, phenomenon existed among Black boys.
4. There are 463 children named DeShawn, 458 of whom are Black. The
name Tyrone is given to 502 Black boys and only 17 Whites. 310 out of 318
Shanice’s are Black, as are 431 out of 454 girls named Precious, and 591 out of 626
girls named Deja.
5. The most extreme case is for the name Molly, in which only 9 of 2,248
children given the name are Black.
770 QUARTERLY JOURNAL OF ECONOMICStize their children with such names, simple price theory models,
and signaling models, all contradict the data in important ways.
The paper concludes by analyzing the relationship between
distinctively Black names and life outcomes. Previous studies
have found that distinctively Black names are viewed negatively
by others (e.g., Busse and Seraydarian ). Most persuasive
are audit studies in which matched resumes, one with a distinctively Black/ethnic minority name and another with a traditionally White name, are provided to potential employers [Jowell and
Prescott-Clarke 1970; Hubbick and Carter 1980; Brown and Gay
1985; Bart et al. 1997; Bertrand and Mullainathan 2003]. Such
studies repeatedly have found that resumes with traditional
names are substantially more likely to lead to job interviews than
are identical resumes with distinctively minority-sounding
names. The results suggest that giving one’s child a minority
name may impose important economic costs on the child. In our
data, however, we ?nd no compelling evidence of a negative
relationship between Black names and a wide range of life outcomes after controlling for background characteristics. Although
seemingly in con?ict with prior audit studies using Black names
on resumes, there are three interpretations of the data that
reconcile the two sets of results: (1) Black names are used as
signals of race by discriminatory employers at the resume stage,
but are unimportant once an interview reveals the candidate’s
race, or (2) Black names provide a useful signal to employers
about labor market productivity after controlling for information
on the resume, or (3) names themselves have a modest causal
impact on job callbacks and unemployment duration that we are
unable to detect.
The remainder of the paper is structured as follows. Section
II describes the data used in the analysis. Section III summarizes
the basic patterns observed in the data. Section IV attempts to
reconcile the stylized facts with a range of potential theories.
Section V analyzes the relationship between names and life outcomes and attempts to reconcile our results with previous audit
studies. Section VI concludes. A data appendix describes the
details of our sample construction.
II. THE DATA
The data used in this paper are drawn from the Birth Statistical Master File maintained by the Of?ce of Vital Records in
the California Department of Health Services. These ?les provide
DISTINCTIVELY BLACK NAMES 771information drawn from birth certi?cates for all children born in
California over the period 1961–2000 —over sixteen million
births. With the approval of the California Committee for the
Protection of Human Subjects, personal identi?ers including
mother’s ?rst name, mother’s maiden name, and child’s full name
have been added to the public use versions of the data. Details of
the data set are provided in the appendix.
The information included varies by year and has generally
been increasing over time. For our entire sample, we have information on the baby’s ?rst name, race, gender, date of birth,
hospital of birth, and birth weight, as well as the mother’s maiden
name, parental ages, and inferred marital status. By 1989, information on parental education, residential zip code, and source of
payment were added to the data. Also starting in 1989 we know
the mother’s ?rst name and exact date of birth, two critical
elements for linking information from a woman’s own birth certi?cate to that of her children in those cases in which a woman is
both born in California and later gives birth there. This allows us
to look at the relationship between circumstances at a woman’s
birth (e.g., her own name, her mother’s level of education, her
mother’s marital status, racial segregation, etc.) and the situation
in which that same woman lives in when she gives birth decades
It also enables us to link information from all births to the
same mother that took place in California, which permits the
comparison of naming patterns controlling for mother-?xed
We restrict our sample to non-Hispanic Blacks (referred to
simply as Blacks).
In determining how Black a name is, our
comparison group is non-Hispanic Whites. Summary statistics for
the Black babies are provided in Table I.
We divide the sample
into four sets of years: 1961–1967, 1968 –1977, 1978 –1988, and
6. Unfortunately, the father’s ?rst name is not included in the data, so a
parallel analysis cannot be performed for males.
7. There is some ambiguity in racial and ethnic categorizations when children are born to parents of different races. We use the classi?cation of a child’s
race and ethnicity on the birth certi?cate to assign these categories, except in the
years 1999 and 2000 when the information on child’s race is missing. In those
years, a child is considered Black if either parent is Black. Before 1989 we do not
have explicit identi?ers for Hispanics. Using information from later years of data,
however, we are able to effectively identify Hispanic surnames and drop from the
sample any child born to a parent with a surname or maiden name that is more
than 10 percent Hispanic.
8. The percentages of black babies born in a hospital or county are time
varying variables measured on an annual basis using the full sample of California
births. Within our four groupings of years, we provide the mean over the relevant
772 QUARTERLY JOURNAL OF ECONOMICSTABLE I
SUMMARY STATISTICS FOR BLACK BIRTHS, CALIFORNIA, 1961–2000
Variables 1961–1967 1968–1977 1978–1988 1989–2000
Female 0.49 0.49 0.49 0.49
(.50) (.50) (.50) (.50)
Age of mother at time of birth 24.43 23.25 24.43 25.70
(6.12) (5.56) (5.47) (6.16)
Age of father at time of birth 28.47 26.85 27.72 28.70
(7.49) (7.21) (7.29) (7.60)
Mother born in California 0.14 0.39 0.51 0.62
(0.35) (0.49) (0.50) (0.48)
Mother unmarried at time of birth 0.31 0.46 0.56 0.58
(0.46) (0.50) (0.50) (0.49)
Birth weight (in grams) 3098.87 3127.58 3181.53 3223.00
(581.26) (598.12) (587.49) (591.27)
Total number of children 3.20 2.29 2.11 2.29
(2.36) (1.69) (1.34) (1.50)
Months of prenatal care 5.87 6.77 7.08 7.28
(1.95) (1.68) (1.59) (1.59)
Teen mother at time of birth 0.23 0.29 0.20 0.18
(0.42) (0.45) (0.40) (0.38)
County hospital 0.42 0.16 0.11 0.09
(0.49) (0.37) (0.32) (0.29)
White mother — 0.10 0.13 0.20
— (0.30) (0.33) (0.40)
White father — 0.02 0.02 0.04
— (0.14) (0.15) (0.19)
Mother’s years of education — — — 12.58
— — — (1.99)
Father’s years of education — — — 12.60
— — — (2.55)
Privately insured — — — 0.43
— — — (0.49)
Per capita income in zip code — — — 13166.30
(All residents in 1989, 1989 dollars) — — — (5277.24)
Per capita income in zip code — — — 11577.52
(Blacks in 1989, 1989 dollars) — — — (4190.11)
Percent of Black population in zip code — — — 37.84
— — — (34.55)
Percent of Black babies in birth county 12.83 17.65 23.57 27.25
(4.18) (6.73) (8.88) (9.97)
Percent of Black babies in birth hospital 37.94 36.86 40.11 41.47
(28.02) (27.63) (27.50) (27.65)
Black Name Index 60.87 66.65 68.13 70.49
(27.73) (31.27) (31.30) (31.49)
Black Name Index—Median 60.19 70.24 73.40 82.28
Number of observations 164,648 253,735 402,120 488,959
All data are drawn from California birth certi?cate records, except for the information on zip codes which
combines birth certi?cate information with data from the 1990 Census. The sample in columns 1– 4 represent
all Blacks born in California between 1961–1967, 1967–1977, 1978 –1988, and 1989 –2000, respectively. The
numbers in parentheses are standard deviations. See the data appendix for further details of the construction
of the samples and variables.
DISTINCTIVELY BLACK NAMES 7731989 –2000. The cutoffs for these groups have been chosen with
three goals in mind: (1) roughly equalizing the time periods in
each group, (2) matching the cutoffs to breaks in trend in the
aggregate data, and (3) grouping years in which similar sets of
covariates are available. Excluded from the data set are a small
percentage of observations missing information on names. When
other variables are missing, we opt to leave the observation in the
analysis, including an indicator variable for a missing value.
The bottom row of Table I presents our summary measure of
how distinctively Black ?rst names are. The measure we choose,
which we term our “Black name index” (BNI) is
where name re?ects a particular ?rst name and t re?ects the year of
birth. The index ranges from 0 to 100. If all children who receive a
particular name are White, then BNI takes on a value of 0. If only
Black children receive a name, BNI is equal to 100. If Whites and
Blacks are equally likely to choose a name, BNI equals 50. If Blacks
are four times as likely to select a name, then BNI takes on a value
of 80 (e.g., .4/[.4 .1] 100 80).
A BNI of 90 implies Blacks choose
a name nine times more often. This measure is invariant to the
fraction of the population that a particular minority group comprises, and to the overall popularity of a name. Names that are
pronounced the same but spelled differently are treated as separate
names. The bottom row of Table I shows that the mean BNI for
Blacks rises from 60.9 in the early period (implying that the mean
Black name is given to Blacks about 50 percent more often than it is
given to Whites) to 71.0 in the last period (implying that these
names are given to Blacks about two and one-half times more
frequently than Whites).
Figure I(A) more clearly demonstrates the dramatic differences between Black and White name choices. The ?gure presents a smoothed plot of the probability distribution function of
Black and White names. The horizontal axis re?ects how Black
an individual’s name is. The vertical axis measures the density of
names chosen by race. More than 40 percent of Whites are given
names that are at least four times as likely to be given to Whites
9. In computing BNI for a particular child, we exclude that child from the
calculation. When a name is unique, meaning that only one child receives that
name in a particular year, we assign the name a value of 0 if the person getting
the name is White and 100 if the baby is Black. We explore unique names in
greater detail later in the paper.
774 QUARTERLY JOURNAL OF ECONOMICSFIGURE I
Black Name Index (A), Asian Name Index (B), and Hispanic Name Index (C)
Distributions, 1989 –2000
DISTINCTIVELY BLACK NAMES 775(between 0 –20). The fraction of Whites steadily shrinks as one
moves from left to right in the ?gure. More than half of all Blacks
have names that are at least four times as likely to be given to
Blacks (between 81–100). For both races there is very little
weight in the middle of the distribution (41– 60), implying that
there are relatively few individuals carrying names that are
similarly likely for Blacks and Whites.
One might suspect that the sharp differences across races in
Figure I(A) may in part be an artifact of how we construct our
measure of Black names using the observed empirical distribution. In other words, we might miscategorize a name as being
distinctively Black or White simply because for many names we
observe only a few individuals with that name. Limiting the
sample to names that appear at least twenty times in the data,
however, does little to change the picture. Figure I(B), which is
identical to Figure I(A) except that it compares the naming patterns of Whites with that of American-born Asians, further demonstrates that the result for Blacks is not an artifact of our
measure. With the exception of a small fraction (approximately
10 percent) of the Asian population adopting names that are rare
among Whites, name choices of American-born Asians strongly
parallel White name choices. A comparison of native-born Hispanics and Whites in Figure I(C) shows differences in naming
patterns among these two groups, although there is still substantially more overlap than for Blacks and Whites.
An important racial difference in naming patterns is the
greater usage of unique or nearly unique names in the Black
community (see also Lieberson and Michelson ). Figures
II(A) and II(B) report, by race and gender, the number of children
born in California in that same year (regardless of race) with that
child’s name. Remarkably, nearly 30 percent of Black girls receive
a name that is unique among the hundreds of thousands of
children born annually in California. Among Whites, that fraction
is only 50 percent. Similarly, the fraction of unique names among
Black boys is six times higher than for White boys, although only
about half the rate of Black girls. The median Black child shares
10. We have also compared the names chosen by Whites with different levels
of education. There are systematic differences in name choices (larger, in fact,
than between Asians and Whites overall), but these differences are much smaller
than either the Black-White or Hispanic-White gap.
776 QUARTERLY JOURNAL OF ECONOMICShis or her name with 23 other children; the number is almost
?fteen times greater for Whites (351).
Perhaps the most interesting ?ndings in the data are the
11. The differences between Blacks and Whites in Figure II are not primarily
due to the fact that there are many more Whites than Blacks born in California
each year. If we randomly select a subset of Whites equal in size to the number of
Blacks born each year, a similar pattern of results persists.
Distribution of Male (A) and Female (B) Babies by How Many Share
a Name, 1989 –2000
(among children of all races born in California in a year)
DISTINCTIVELY BLACK NAMES 777changes in the distribution of name choices over time. For children born in each year between 1961 and 2000, we compute our
Black name index and then rank order the Blacks in our sample
according to how Black their name is. Figure III presents the
mean BNI by year for each of the four quartiles of the distribution. The top quartile is very close to 100 throughout the entire
time period (i.e., almost one-quarter of Blacks had names virtually never given to Whites throughout the sample) and thus
exhibits little time-series variation. For the other three quartiles,
Black naming patterns were largely stable throughout most of
the 1960s. Beginning in the late 1960s, the second quartile from
the top experiences a sharp rise in how Black the name choices
are. Between 1968 and 1977, the mean BNI within this quartile
goes from roughly 75 (meaning the name was three times as
likely to be given to a Black baby as a White baby) to almost 95
(?fteen times more likely to be given to a Black baby). The third
quartile also rises over that time period, but not as sharply, and
also steadily increases over the period 1985–2000. The bottom
Black Naming Patterns, 1961–2000 by Quartile of Black Name Index
778 QUARTERLY JOURNAL OF ECONOMICSquartile, in contrast, remains almost unchanged throughout the
Figure IV is identical to Figure III, except that it disaggregates the data by the degree of racial segregation in the
hospital in which a Black baby is born. We sort by racial
segregation of the hospital and then by quartile of BNI. We
show only the top and bottom deciles (i.e., the 10 percent of
Blacks giving birth in hospitals with the greatest percent Black
and the lowest percent Black, respectively) to highlight the
extremes of the distribution. The most important observation
emerging from Figure IV is the widening gap between the
names given to Black babies born in predominantly Black and
predominantly White hospitals over time. At the beginning of
the sample, name choices differ little by the degree of racial
segregation. For example, in the bottom quartile, Blacks born
in racially segregated hospitals have a mean BNI of 26 versus
12. The divergence in naming patterns in the late 1960s and early 1970s is
unique to Blacks. Among Hispanics and Asians, name choices relative to Whites
change little between 1961 and 1978. This suggests that a shift in Black name
choices drives the patterns in Figure III. In the 1990s, however, Hispanic names
diverge somewhat from those of Whites, suggesting that changes in White naming
patterns may be a factor in that time period.
Changes in Black Naming Patterns by Racial Composition of Neighborhood
and by Quartile of Black Name Index
DISTINCTIVELY BLACK NAMES 77923 for Blacks born in predominantly White hospitals. By 1978
these gaps have widened substantially, particularly in the
third quartile where Blacks in Black hospitals have shifted
more than twenty points relative to the beginning of the sample, but names of Blacks in White hospitals are essentially
unchanged. Interestingly, among the Black babies given the
least distinctively Black names (the bottom quartile), those
born in White hospitals actually see a discernible decrease in
how Black their names are, in contrast to the rest of the
The sharp rise in the prevalence of distinctively Black names is
driven in part by the increasing use of unique names among Blacks.
Figures V(A) and V(B) present time-series data on the percentage of
babies with unique ?rst names by gender and racial mix of the birth
hospital, where a unique name is de?ned as a name that no other
baby born in California that year shares. The fraction of Black baby
girls receiving unique names rose for the ?rst ?fteen years of the
sample. Initially, rates of unique naming were similar among Blacks
in predominantly Black and predominantly White neighborhoods
(around 10 percent); that gap grows over time. Nonetheless, even for
Blacks in White neighborhoods, almost one-quarter of baby girls
received unique names. Among Whites, the rates are around 5
percent, although this (as well as the Black numbers) is likely to be
an upper bound due to typographical errors being counted as unique
Figure V(B) documents a parallel, though less pronounced,
phenomenon for Black boys. In 1961 the percentage of unique
names ranged from 5– 6 percent, irrespective of hospital. By 2000,
one-?fth of Black boys born in predominantly Black hospitals receive unique names.
Unique names, while an important part of the explanation
for the divergence in Black and White naming patterns, are not
the entire story. Figure VI presents time-series evidence on the
fraction of Blacks who have nonunique names that are above 80
on the BNI index, as well as the fraction of Blacks with unique
names. The share of babies given distinctively Black, but nonunique names rises from 15 percent to 22 percent from the be-
13. The choice of names by Whites over time does not exhibit this pattern of
bifurcation that is present in Black naming in Figures IV and V. The BNI for
Whites is almost uncorrelated with the racial segregation of the hospitals in which
they give birth throughout the entire time period.
14. There are two dif?culties that arise in trying to purge the data of typographical errors. First, the scale of the data is enormous. Second, we have no way
of knowing whether a particular name represents a typo (e.g., “Brian” mistyped as
“Brain”) or linguistic innovation.
780 QUARTERLY JOURNAL OF ECONOMICSginning of the sample to the peak in the mid-1970s. Unique
names rise from 7 percent to 18 percent over that same period.
After a dip in the 1980s, unique names gain in prominence in the
1990s, whereas nonunique distinctively Black names do not rise
in popularity in the later years.
Percentage of Unique Girl (A) and Boy (B) Names by Racial Mix of Hospital
DISTINCTIVELY BLACK NAMES 781Table II examines the relationship between parental characteristics, birth circumstances, and the names given to children at
four different points in time. We estimate equations of the form:
(2) BNIiht Xiht Zht
where i, h, and t index individuals, hospitals, and time, respectively; Xiht
represents an array of individual level background
are hospital-level (potentially time varying) controls, and Yc t
denotes county-level (possibly time varying) controls. The standard errors are clustered by hospital-year. The ?rst
four columns of the table correspond to different sample periods.
Column 1 re?ects Black children born between 1961 and 1967,
prior to the sharp changes in Black naming behavior. Column 2
has births occurring between the years 1968 and 1977, the years
in which the transition occurred. Columns 3 and 4 capture the
periods 1978 –1988 and 1989 –2000, respectively. We separate
these two time periods because of the availability of a more
complete set of covariates after 1989. Also, after 1989 we have the
Percent of Black Babies Given Unique Names and Nonunique Distinctively
Black Names, 1961–2000
782 QUARTERLY JOURNAL OF ECONOMICSnecessary information to link multiple births to the same women,
allowing for the inclusion of mother-?xed effects in column 6. All
of the controls included in the regression are taken from a child’s
birth certi?cate and thus are determined at the time of birth. For
the entire period, covariates available include parents’ marital
status, age, and race, mother’s place of birth, her total number of
children, months of prenatal care, the baby’s birth weight, the
percent Black at the birth hospital, the percent Black in the
county, and whether the child is born in a county hospital. In the
later years of the sample, the set of included controls is much
richer: income and percent Black at the zip code level, highest
grade completed by mother and father, and expected source of
payment for the delivery.
Columns 1– 4 hold the set of covariates constant and compare
the relative importance of these variables in predicting BNI over
the four periods. In almost all cases, variables associated with low
socioeconomic status are also associated with Blacker names.
Moreover, the link between low socioeconomic status and Black
names becomes much stronger over time. The coef?cients on
mother’s age, birth weight, and single mother are less than onehalf as large in the ?rst period (column 1) as they are in the last
period (column 4). Father’s age has no impact in the early period,
but does have a negative coef?cient in the later periods. Note also
that the R
in the regressions increases steadily over time, meaning that these characteristics explain a growing fraction of the
variation in names. A ?nal implication of the table is that names
are becoming more distinctively Black over the course of the
sample. For instance, a woman with the mean sample characteristics in the 1960s would be predicted to choose a name with a
BNI of 60.9 in the 1961–1967 period. A woman with those same
characteristics giving birth in the 1990s will on average choose a
name with a BNI of 71.4. Likewise, for a woman with the average
traits of mothers giving birth in the 1990s, the predicted BNI of
the name is 70.5 for a baby born in the 1990s compared with 61.8
if that baby had been born in the 1960s.
The speci?cation estimated in columns 5 and 6 are similar to
those in the previous columns of the table, except the richer set of
15. The results in Table II are similar if the sample is restricted to names
given to twenty or more babies in a given year. Patterns are also similar if we use
as the dependent variable an indicator for whether or not a child has a unique
name. Although not shown in tabular form, we also ?nd that many of the same
factors that predict the choice of names among Blacks also predict the choice of
names among Whites, although for Whites the magnitude of the impacts is
substantially smaller in magnitude.
DISTINCTIVELY BLACK NAMES 783TABLE II
DETERMINANTS OF NAME CHOICES AMONG BLACKS
Variable 1961–1967 1968–1977 1978–1988 1989–2000
Female 1.29 3.31 4.84 3.06 3.17 4.04
(0.14) (0.14) (0.11) (0.10) (0.10) (0.14)
Percent of Black babies in birth hospital 0.045 0.060 0.081 0.091 0.027 0.018
(0.004) (0.005) (0.003) (0.004) (0.004) (0.005)
Percent of Black babies in county 0.064 0.142 0.035 0.012 0.008 0.004
(0.020) (0.016) (0.010) (0.010) (0.010) (0.016)
Mother born in California 2.16 0.46 0.06 0.46 0.11 —
(0.35) (0.16) (0.11) (0.11) (0.10) —
Mother’s age at time of birth 0.35 0.54 0.63 0.74 0.50 0.15
(0.02) (0.02) (0.01) (0.01) (0.01) (0.05)
Father’s age at time of birth 0.00 0.17 0.13 0.19 0.16 0.06
(0.02) (0.01) (0.01) (0.01) (0.01) (0.02)
Months of prenatal care 0.07 0.27 0.04 0.17 0.04 0.00
(0.04) (0.04) (0.03) (0.03) (0.03) (0.05)
County hospital 1.16 0.05 0.68 0.08 0.90 0.60
(0.20) (0.29) (0.19) (0.30) (0.29) (0.35)
Birth weight in kilograms 0.42 1.12 1.91 1.78 0.59 0.02
(0.12) (0.11) (0.09) (0.08) (0.08) (0.16)
Total number of children 0.22 0.73 1.32 1.84 0.85 0.06
(0.04) (0.05) (0.05) (0.04) (0.04) (0.11)
Single mother 2.10 4.21 5.21 4.73 2.95 0.20
(0.28) (0.15) (0.13) (0.12) (0.11) (0.21)
Percentage of Black babies in zip code — — — — 0.0029 0.0103
— — — — (0.0024) (0.0045)
784 QUARTERLY JOURNAL OF ECONOMICSTABLE II
Variable 1961–1967 1968–1977 1978–1988 1989–2000
Per capita income (all residents, 1989) — — — — 0.0622 0.0116
( 1000) — — — — (0.0163) (0.0340)
Per capita income (Black residents, 1989) — — — — 0.2294 0.0830
( 1000) — — — — (0.0187) (0.0389)
Mother’s years of education — — — — 0.850 0.060
— — — — (0.030) (0.073)
Father’s years of education — — — — 0.295 0.029
— — — — (0.023) (0.043)
Privately insured — — — — 2.98 0.55
— — — — (0.15) (0.22)
White mother — — — — 12.22 —
— — — — (0.13) —
White father — — — — 17.94 6.28
— — — — (0.26) (0.81)
Constant 66.61 76.11 81.61 88.18 104.61 —
(0.78) (0.59) (0.51) (0.50) (0.62) —
0.0117 0.0354 0.0464 0.0592 0.0951 0.7764
Birth sample used 1961–1967 1968–1977 1978–1988 1989–2000 1989–2000 1989–2000
Include mother-?xed effects? No No No No No Yes
Number of observations 164648 253703 402120 488959 488959 488485
The dependent variable in all columns is the Black Name Index of the name given to the child at birth. The Black Name Index ranges from 0 for names that are only given to
Whites to 100 for names that are only given to Blacks. All variables included on the right-hand side of the regression are known at the time of a baby’s birth. Included in the regression,
but not reported in the table are indicator variables for missing values. Standard errors are clustered to take into account correlation across people born in the same hospital in the
DISTINCTIVELY BLACK NAMES 785covariates is used. Blacker names are associated with lowerincome zip codes, lower levels of parental education, not having
private insurance, and having a mother who herself has a Blacker
The last column of Table II adds mother-?xed effects to the
speci?cation. Thus, the identi?cation comes from changes in a
mother’s situation across different births. To the extent that
mothers anticipate the changes that occur in their circumstances
between births and factor these expectations into the name given
to their ?rst child, the ?xed-effects coef?cients will be biased
toward zero. The estimates in column 6 are substantially smaller
in magnitude than in the earlier columns, with the exception of
variables re?ecting how Black the neighborhood is and the coef-
?cient on female. The coef?cient on mother’s age ?ips sign, implying that women who have babies early in life tend to choose
Black names relative to other women, but that a given woman
picks slightly Blacker names for her children as she grows
In addition, the inclusion of mother-?xed effects raises
from .095 to .776 —there is a great degree of continuity in
the names mothers choose for their children, implying that person-speci?c tastes are quite important determinants of name
choice. The results with mother-?xed effects suggest either that
temporary changes in circumstances have a relatively small impact on name choices, or that our measures of current circumstances are noisy.
III. UNDERSTANDING THE PATTERNS IN THE DATA THROUGH
THE LENS OF ECONOMIC THEORY
A number of stylized facts emerge from the analysis of the
preceding sections. Blacks, much more than other minorities,
choose distinctive names for their children. The distinctiveness of
Black names has risen greatly over time, most notably in the late
1960s and early 1970s. These shifts in naming patterns have not,
however, been uniform. In particular, among the quarter of the
Black population choosing the names most common among
Whites, the opposite pattern is evident. Further, Blacks living in
highly segregated Black communities today are much more likely
to have distinctively Black names than those in integrated communities, whereas this was not the case in the early 1960s.
16. This result holds up when we include a full set of year dummies, implying
that the increases in BNI are age effects of the mothers and not time effects.
786 QUARTERLY JOURNAL OF ECONOMICSFinally, until the late 1970s the choice of Black names was only
weakly associated with socioeconomic status; in the 1980s and
1990s distinctively Black names have come to be increasingly
associated with mothers who are young, poor, unmarried, and
have low education.
In this section we consider the extent to which existing theories can successfully account for this disparate set of facts.
III.A. The Ignorance Model
One explanation for the prevalence of distinctively Black
names is ignorance on the part of Black parents, who fail to
appreciate the costs they are imposing on their children through
such choices. Audit study results, for instance, suggest that Black
names may be punished in the labor market.
This theory fails to adequately explain the sharp increase in
distinctively Black names in the late 1960s and early 1970s.
There is little reason to believe that Black parents became systematically less informed about the consequences of distinctively
Black names at that time. This theory is also at odds with the fact
that those adopting Black names in the early 1970s were, for the
most part, representative of the Black community, not a small
subset of parents likely to be particularly misinformed.
III.B. Price Theory Model
Consider the following skeletal outline of a price theory
model of names, which we derive formally in an earlier version of
this paper [Fryer and Levitt 2002]. Parents give names to their
children at birth to maximize the child’s expected utility. Individuals are born into neighborhoods that differ in racial composition.
People live and work in the same neighborhoods. Moving between
neighborhoods is costly. The returns to ability are assumed to be
higher in predominantly White neighborhoods. White names pro-
17. On the other hand, one cannot a priori rule out that this explanation has
potential relevance for explaining at least some of the patterns of the last two
decades. If it became apparent in the 1980s that there were costs to having a Black
name, one might expect that parents who were likely to be best informed about
these costs (e.g., older working parents living in less racially isolated neighborhoods) would choose such names less frequently, whereas learning on this dimension might be more gradual for teenage mothers in the inner city. In absolute
terms, this explanation fails, because the adoption of Black names rose throughout the 1990s. At least in relative terms, however, there was a shift in the 1980s
and 1990s toward an increasing concentration of distinctively Black names among
parents least likely to be well informed about the potential stigma of such names
in broader society. In light of results presented later in the paper that call into
question the costs of adopting distinctively Black names, however, we are quite
skeptical of this theory as an explanation for the observed phenomena.
DISTINCTIVELY BLACK NAMES 787vide bene?ts in interactions with Whites; Black names are bene-
?cial when interacting with Blacks. We also assume that the
value of a White name is increasing in ability, motivated by the
audit study literature which suggests that the primary cost of a
distinctively Black name is via the labor market. A child’s ability
is not known with certainty at birth, although the distribution
from which the child’s ability will be drawn is known.
In this model, parents will opt for Whiter names when (i)
their children are more likely to be high ability, (ii) the cost of
moving to predominantly White neighborhoods falls, (iii) returns
to ability rise in the labor market, (iv) the relative cost of having
a White name when interacting with Blacks falls, and (v) the
bene?t of having a White name when interacting with Whites
The predictions of this model face mixed success in terms of
the patterns observed in the data. Consistent with the theory is
the fact that those in racially isolated communities are especially
likely to adopt distinctively Black names in recent decades, and
that such names are most common among groups likely to face
the greatest barriers to participating in traditional labor markets. This theory, however, does quite poorly in explaining the
sharp rise in distinctively Black names in the late 1960s and
early 1970s—a period immediately following the passage of national Fair Housing laws in 1968, falling social barriers to integration, and increased economic opportunity for Blacks. Empirically, urban racial segregation which had been rising began to fall
around this time and has steadily declined for three decades
[Cutler, Glaeser, and Vigdor 1999].
In light of these apparent
reductions in the costs of switching between neighborhoods, one
would have expected a shift away from distinctively Black names
at precisely the point where such names were becoming most
Additionally, it is not clear that the price theory model provides an adequate explanation as to why Black names are much
more distinctive than Asian or Hispanic names, when presumably many of the same trade-offs might also exist among those
18. Although the level of residential racial segregation has declined at a
relatively slow rate, to the extent that these persistent declines were anticipated
and parents are concerned with the impact a name will have on their children as
adults in the labor market, one would nonetheless expect to see an immediate,
abrupt shift in naming patterns.
788 QUARTERLY JOURNAL OF ECONOMICSIII.C. A Signaling Model
A third model to consider is a simple signaling model in
which distinctively Black names serve as a signaling device, but
are otherwise not productive, along the lines of prior research by
Iannaccone , Berman , and Fryer .
predominantly Black neighborhood populated by Black individuals of one or two types: those who have a strong af?nity for the
Black community (the “black” type) and those who do not (the
“white” type). An individual’s type is ?xed at birth and cannot be
changed. Each individual knows her own type, but type is not
observable to others. An individual’s utility is determined by his
type and the neighborhood’s perception about his type. Regardless of one’s actual type, social interactions in the Black community yield higher utility if others believe that one has an af?nity
for the Black community.
Thus, all else being equal, both types
prefer to be perceived as being a “black” type.
One way in which an individual signals his or her type is by
the names that they choose for their children. In the model, each
parent has one child and bestows a name on that child. The
(suitably anthropomorphized) community observes the name that
each parent gives his or her child, and based on that signal, draws
unbiased inferences about the parent’s type. As in the price
theory model, we assume that White names provide labor market
bene?ts. The total cost and marginal cost of giving a child a
Blacker name is lower for a parent with the “black” type.
Either separating or pooling equilibria may arise in such
models. In any separating equilibrium, parents whose type is
“black” are willing to give otherwise costly names to their children simply because it allows them to distinguish themselves
from parents who identify as “white,” and derive more utility
from social interactions. As a result, peers come to regard Black
names as a signal of community loyalty. In any pooling equilibrium, the payoff to social interactions is determined by the underlying population distribution of types. Pooling is likely to
occur, in our model, when the marginal rates of substitution for
both types of parents are similar.
The predictions of the signaling model ?t some of the basic
19. For a formal treatment of this model, see the earlier version of this paper
[Fryer and Levitt 2002].
20. For example, those with an af?nity to the Black community may be more
likely to contribute to local public goods than those with “white” identities,
inducing better treatment from their neighbors. For instance, Anderson 
talks about the importance of having others “watch your back.”
DISTINCTIVELY BLACK NAMES 789patterns observed in the data. Black name choices in the 1960s,
for instance, look roughly consistent with a pooling equilibrium in
which one’s name is not a strong signal. Any mechanism that
ampli?ed the differences in the cost of signaling between the two
types could cause a bifurcation in the distribution of Black names
such as occurred in the early 1970s, with “black” types moving to
distinctively Black names and “white” types shifting toward
Whiter names (if they previously had been in a pooling equilibrium) or continuing to choose traditional white names (if they
formerly were in a separating equilibrium). Such a change could
have come as a result of the increased opportunities for integration due to the civil rights movement [Fryer 2003]. Those Blacks
with the most to gain from integration would opt for Whiter
names. Somewhat counterintuitively, for those Blacks who continue to signal a “black” type, to sustain the new equilibrium
requires an even costlier (i.e., Blacker) name choice since the
outside option is now more attractive.
The signaling model appears to fall short in explaining four
dimensions of the data. First, in the 1980s and 1990s, individuals
who are most likely to adopt distinctively Black names (young,
unmarried women in predominantly Black neighborhoods) are
those with the least need to signal af?nity with the Black community or their commitment to remaining in the neighborhood.
Second, the signaling model has a hard time explaining why
Black names became more prevalent among many different types
of Blacks, including those who live in mostly White communities.
Third, in order for the Black names signal to be credible, it must
impose costs on those who carry the names. In Section IV of this
paper, however, we are unable to detect evidence that Black
names are costly. Finally, the signaling model provides little
rationale as to why Blacks might engage much more extensively
in signaling than do either Asians or Hispanics.
III.D. An Identity Model
The primary shortcoming of the signaling model in explaining the data is that, for a large segment of the Black community,
distinctively Black names appear to be viewed as a bene?t rather
than a cost. In the signaling model, an investment must be costly
to provide a credible signal. Using a similar framework, but
allowing Black names to be a bene?t for those with the “black”
type and a cost for those with the “white” type converts the
signaling model into a simple identity model.
In particular, we have in mind the framework of Akerlof and
790 QUARTERLY JOURNAL OF ECONOMICSKranton . In their language, identities are accompanied by
certain “prescriptions” that de?ne appropriate behaviors for a
person of that type. When an individual takes actions in line with
these prescriptions (e.g., a “black” type choosing a distinctively
Black name, or a “white” type choosing a White name), there is a
To justify the patterns in the time series circa 1970 through
this model, there must be a shock to the identity prescriptions
(i.e., what it means to be Black) around this time period. The rise
of Black Power appears to be precisely that sort of shock. The
underlying philosophy of the Black Power movement was to encourage Blacks to accentuate and af?rm Black culture and ?ght
the claims of Black inferiority [Van Deburg 1992]. Within the
Black community, there were widespread changes in hair styles
and the rising popularity of afro-centric clothing between 1968 –
1975 [Van Deburg 1992; Woodward 1974]. The adoption of distinctively Black names would be completely consistent with these
other cultural phenomena. The identity model may also help to
explain why naming patterns among Blacks are quite distinctive
from Whites, but Asians name their children in much the same
manner as Whites. For instance, if Asian “prescriptions” stress
?nancial success and assimilation, Asian names would be expected to mirror those of Whites.
Another fact consistent with a Black Power explanation is
that the concentration of Blacks by county is a much stronger
predictor of Black names in the 1968 –1977 period than the rest of
the sample. In column 2 of Table II, the coef?cient on that variable is .142 (standard error of .016) for 1968 –1977, but never
larger than .064 in any other period. The county-level trends also
exhibit a basic consistency with a Black Power story. Alameda (in
which Oakland is located), Los Angeles, and San Francisco counties were the centers of the Black Power movement. Black names
increased earlier and to a greater extent in these three counties
than the rest of the state.
The identity model may also apply to the increases in BNI in
the 1990s, as there is suggestive evidence that there was a secondary Black cultural movement during this time. Indeed, this is
precisely the period in which Blacks (headed by Jesse Jackson
and Detroit Mayor Coleman Young) demanded to be referred to as
African-American. This change was meant to tie Blacks more
closely to their African cultural heritage. Enrollment in historically Black colleges and universities, which had been declining for
a decade, rose over 20 percent between 1986 and 1994 [Hoffman
DISTINCTIVELY BLACK NAMES 7911996]. There was an emergence in the entertainment industry of
politically motivated music (Public Enemy, for example) and ?lm
(i.e., Do the Right Thing, Spike Lee), which highlighted the abhorrence in black communities of the status quo. Recall, a similar
spark ignited the Black Power movement, as some Blacks were
frustrated with the niceties of the civil rights generation. In a
related paper, McAdams, Fryer, and Levitt  provide a more
thorough investigation of the black power movement between
1968 –1975 and the Black cultural movement in the 1990s; as
explanations of the time-series changes in BNI.
In summary, although the evidence in favor of the identity
model is far from overwhelming, it is the only theory examined
which does not yield predictions that are directly at odds with the
observed patterns in the data.
IV. THE RELATIONSHIP BETWEEN NAMES AND ADULT OUTCOMES
In light of audit studies documenting the use of names as a
screening device by employers, one might expect that having a
distinctively Black name should be associated with worse economic outcomes, holding all else equal. In this section we link
information from a woman’s own birth certi?cate to her adult
circumstances as re?ected in the information on the birth certi?-
cates of her children at the time she gives birth.
In order to make this linkage, a woman must be born in
California and later give birth in California. We focus our analysis on women born in 1973 and 1974 —the earliest years for which
we have the necessary information to make reliable links. Of the
women still residing in California who have given birth, we match
at a high rate (over 90 percent).
The subset of women that we
successfully link is not representative of all women born in 1973–
1974. In particular, women who defer childbearing to their late
twenties are excluded from our sample. The women we are able to
link are themselves born to slightly younger, unmarried mothers.
21. Lieberson and Michelson  make a similar point as they relate the
rise in the prevalence of unique names to the rise of the Black Panther Party.
22. According to the 1990 Census, roughly 20 percent of Black women born in
California live outside the state during their childbearing years. Also based on
1990 Census data, 42 percent of Black women born in California have no children
by age 27. If leaving California is independent of the decision to have a child by
age 27, then 46.4 percent of Black women born in California should give birth in
California in our sample. [1–.2] .58. For details of how this linkage is performed,
see the data appendix. A smaller subset of White women are successfully linked
because more Whites move out of state and more White women defer childbearing
until later in life.
792 QUARTERLY JOURNAL OF ECONOMICSThe differences between the whole sample and the linked subset
are consistent with higher fertility rates and lower rates of crossstate mobility among these groups. Importantly, however, after
controlling for socioeconomic characteristics, there is no systematic difference between the ?rst names of the women who are or
are not successfully linked. If we regress an indicator variable for
a successful link (equal to one if a link occurs and zero otherwise)
on the woman’s BNI and background characteristics at the time
of the woman’s birth, the coef?cient on the woman’s BNI is both
substantively and statistically insigni?cant. Nonetheless, it is
important to emphasize that our sample for testing the relationship between names and life outcomes is limited to females born
in California who later give birth there before the age of 27.
Further, our outcome measures are coarse. We do not observe
individual wages or family economic circumstances, but rather,
the median income of their zip code, years of education, etc, which
are highly correlated with the relevant outcomes.
Our approach to testing for a relationship between names
and life outcomes involves predicting adult life outcomes as a
function of everything known about a woman and her parents at
the time of her own birth, including her name:
where i indexes women, h represents hospitals, and the superscripts adul t and bi r th correspond to the time at which the
variable is measured. In some speci?cations we restrict the sample only to Blacks; in other cases we include both Blacks and
Whites including an indicator for race and interactions between
BNI and race. We analyze a wide selection of outcomes as dependent variables. All of the covariates included in the earlier analysis of the cohorts born in the 1970s are also in this speci?cation.
We limit the sample to the last birth that we observe for a
particular woman in order to most closely approximate the longrun outcomes of the women, although the results are not sensitive
to this restriction.
The clear weakness of this empirical approach is that if
unobserved characteristics of the woman are correlated both with
life outcomes and her name, our estimates will be biased. Given
that Black names are associated with lower socioeconomic status
on observable measures, one would expect that Black names are
also likely to be positively correlated with omitted variables that
DISTINCTIVELY BLACK NAMES 793predict worse life outcomes, leading our estimates to exaggerate
the true relationship between a woman’s name and her life outcomes, although one can also construct scenarios in which the
opposite bias could arise.
The results of estimating equation (3) restricting the sample
to Black women are presented for a range of outcome variable in
the top two rows of Table III. The top row does not include any
controls; the second row includes the full set of controls. In both
cases, only the coef?cient on the woman’s own Black Name Index
is presented in the table. In the absence of controls for background characteristics, Blacker names are uniformly associated
with worse adult outcomes. Given the correlation between Black
names, growing up in segregated neighborhoods, and more dif?-
cult home environments, this relationship is expected. What is
surprising, especially in light of the biases discussed above, is
how limited the impact of a woman’s name is on her life outcomes
once we control for other factors that are present at the time of
her birth. When we include covariates in the basic speci?cation
(row 2), we ?nd statistically signi?cant coef?cients for only four
outcomes: percent Black in the hospital the mother gives birth,
whether the woman is unmarried at the time of the birth, per
capita income among Blacks living in her zip code, and how Black
a name the woman chooses for her own child. Even in these cases
of statistical signi?cance, the magnitude of the coef?cients associated with the BNI is substantively small. Changing the BNI
from 50 to 100 raises the percent Black in the hospital where the
mother gives birth by less than one percentage point, the probability of an unmarried birth two-tenths of one percentage point,
and per capita income for Blacks in the zip code by $100. The
largest impact that a woman’s name appears to have is on how
she names her children. An increase of 50 in the BNI raises the
BNI of her children by about 3—a little more than half the impact
that being a single mother has on naming, and the same impact
as having the child in a hospital in which an extra 30 percent of
the births are to Blacks. None of the other variables considered
yield statistically signi?cant coef?cients: years of education of the
woman or the father of her child, mother’s age at ?rst birth,
23. One logical solution to this problem would be to use the name of the
woman’s mother as an instrument. The mother’s name is a strong predictor of her
daughter’s name, but one might plausibly argue that controlling for a wide range
of covariates at the time of the daughter’s birth, the mother’s name will have no
impact on her daughter’s adult outcomes. Unfortunately, the mother’s ?rst name
is not included in our data set until 1982, so this instrumental variables strategy
will not be feasible until more years of time have passed.
794 QUARTERLY JOURNAL OF ECONOMICSprivate insurance coverage, her baby’s birth weight, and number
of total children born to date.
Particularly in light of the biases
likely to be pushing the results toward ?nding a spurious negative relationship between names and outcomes, we conclude that
there is little evidence that how Black one’s name is negatively
impacts life outcomes.
In the remaining rows of Table III, we expand the sample to
include both Whites and Blacks. In addition to the same set of
control variables included in the second row of the table, we add
an indicator variable for a woman’s race as well as interactions
between race and BNI. The race dummy captures systematic
differences in outcomes for Blacks and Whites with otherwise
similar observable characteristics at birth. The interactions between BNI and race allow for a differential impact of name choice
by race. Empirically, we ?nd large coef?cients on the race variable for most outcomes. Controlling for the set of characteristics
observed at the time of a woman’s birth, Black women live in
neighborhoods with 28.8 percentage points more Blacks, give
birth about one year earlier, have babies that weigh almost 200
grams less, are 26 percentage points more likely to be unmarried
when they give birth, nine percentage points less likely to have
private insurance, and live in neighborhoods with per capita
income over $2,000 lower than Whites. The only variables for
which the race dummies are not substantively large is for years of
education. These systematic racial differences may re?ect either
discrimination or unmeasured differences between Blacks and
Whites; we have no power to distinguish between these competing hypotheses. Note, however, that the weak relationship between names and outcomes persists. Interestingly, there is generally a stronger relationship between BNI and life outcomes for
Whites than Blacks, although in both cases the magnitude of the
effects is small.
24. The ?ndings are robust to relaxing the restriction that BNI affect the
outcome measures linearly. If we replace our measure of BNI with a set of
mutually exclusive indicator variables corresponding to having a unique name, a
BNI greater than 80 but not unique, a BNI between 50 and 80, and the omitted
category which is a BNI less than 50, the basic conclusions are unchanged.
25. We have also explored whether other aspects of naming have a causal
impact on life outcomes. For example, one might expect that having the “wrong”
kind of name (i.e., a White name in a Black neighborhood and vice versa) will, at
least in terms of utility, adversely affect life outcomes. We attempted to identify
people with the “wrong” names in two different ways. In the ?rst approach, we
calculate the deviation between the BNI that a person actually received and the
BNI that we predict they should have received based on their birth circumstances.
The absolute magnitude of the deviation represents how “wrong” their name is
from an ex ante perspective. An alternative way of characterizing someone as
DISTINCTIVELY BLACK NAMES 795TABLE III
THE RELATIONSHIP BETWEEN NAMES AND LIFE OUTCOMES
zip code as
Percent Black in
mother gives birth
as an adult
gives birth as an
Mean 43.3 47.4 57.0 12.4 12.2 19.6
dev. (35.0) (27.2) (23.3) (1.6) (2.2) (3.0)
Sample restricted to Blacks
Coef?cient on the variable:
Black Name Index No 0.0602 0.0543 0.0458 0.0006 0.0006 0.0020
(0.0099) (0.0080) (0.0101) (0.0005) (0.0007) (0.0008)
Black Name Index Yes 0.0155 0.0172 0.0201 0.0008 0.0000 0.0009
(0.0096) (0.0072) (0.0092) (0.0005) (0.0007) (0.0007)
Sample includes Blacks and Whites
Coef?cient on the variable:
Black Name Index Black Yes 0.0007 0.0076 0.0073 0.0009 0.0004 0.0003
(0.0096) (0.0073) (0.0062) (0.0005) (0.0007) (0.0008)
Black Name Index White Yes 0.0018 0.0151 0.0144 0.0022 0.0013 0.0026
(0.0028) (0.0041) (0.0043) (0.00044) (0.00066) (0.00063)
Black Yes 28.8 20.7 19.0 0.097 0.072 0.911
(1.2) (1.0) (0.9) (0.046) (0.071) (0.078)
796 QUARTERLY JOURNAL OF ECONOMICSTABLE III
time of birth
born so far
Per capita zip
Per capita zip
for her child
3219.4 0.71 0.37 2.01 12587 11170 77.8
(560.4) (0.45) (0.48) (1.16) (4697) (3552) (29.23)
Sample restricted to Blacks
Coef?cient on the variable:
Black Name Index 0.27 0.0007 0.0004 0.0009 7.1 5.0 0.081
(0.16) (0.0001) (0.0001) (0.0003) (1.4) (1.1) (0.009)
Black Name Index 0.04 0.0004 0.0001 0.0005 2.2 1.9 0.062
(0.17) (0.0001) (0.0001) (0.0003) (1.1) (1.4) (0.009)
Sample includes Blacks and Whites.
Coef?cient on the variable:
Black Name Index Black 0.15 0.0002 0.0000 0.0005 0.2 1.1 0.058
(0.17) (0.0001) (0.0001) (0.0003) (1.4) (1.1) (0.009)
Black Name Index White 0.15 0.0002 0.0004 0.0008 5.0 1.8 0.034
(0.15) (0.0001) (0.0001) (0.0002) (1.4) (1.8) (0.007)
Black 194.5 0.26 0.09 0.21 2364.3 687.9 41.37
(15.1) (0.01) (0.02) (0.03) (150.7) (132.6) (0.82)
The dependent variable is listed at the top of each column. The values reported in the table are the coef?cient on the measure of how Black an individual’s name is. In the top two rows,
the key regressor is the Black Name Index. In the bottom six rows, three indicator variables are included denoting whether a name is unique, greater than 80 on the Black Name Index,
or between 50 and 80. The omitted category is less than 50 in those speci?cations. Results are presented with no controls and including percent of Black babies in birth hospital, percent
of Black babies in birth county, whether mother was born in California, mother’s age at time of birth, father’s age at time of birth, months of prenatal care, whether born in a county hospital,
birth weight, total number of children, and dummy for single mother. The sample in the top panel of the paper is the set of Black women for whom we successfully match their own birth
certi?cate information to that of their children when the women themselves give birth. The sample in the bottom panel includes both Blacks and Whites whom we successfully match from
own birth certi?cate to the child’s. Standard errors are in parentheses. All of the covariates in the regressions (percent Black babies in woman’s birth hospital, percent of Black babies in
county of woman’s birth, whether woman’s mother is born in California, mother’s and father’s age at time of woman’s birth, mother’s months of prenatal care, whether woman’s mother was
married at the time of woman’s birth, whether woman was born in a county hospital, woman’s birth weight, and total number of prior births to the woman’s mother) are known as of
1973–1974 when the women are born. All of the outcome variables correspond to the circumstances when they give birth as adults in the period 1989 –2000.
DISTINCTIVELY BLACK NAMES 797There are three possible interpretations of the data that
reconcile our ?ndings with that of the audit study literature. One
possibility is that the only function names serve is as a noisy
initial indicator of race. In this view of the world, those with Black
names may receive fewer job interviews, but no fewer job offers.
Discriminatory employers will use distinctively Black names as
noisy signals of race, but names become irrelevant once the candidate shows up for an interview and the employer directly observes race.
Indeed, in such a world, there is a bene?t to Blacks
of signaling their race through name choice in order to avoid
undertaking costly interviews unlikely to yield jobs and to signal
race to employers giving preferential treatment to Blacks. A
second interpretation of the data that is consistent with our
?ndings and those of the audit studies is that Black names,
because of self-selection among Black parents, provide useful
signals of human capital to employers, even controlling for race
itself and other information available on resumes.
A ?nal possibility is that names themselves have a modest causal impact on
job callbacks and unemployment duration that we are unable to
detect using the relatively coarse outcome measures available to
us. Note that only in the third of these three interpretations does
a person’s name have any causal impact on life outcomes.
We cannot directly test between these competing hypotheses
for two reasons. First, our data set lacks clean measures of
productivity. We do, however, observe worker characteristics that
having the “wrong” name is to look at cases in which a woman’s name is mismatched ex post with the actual neighborhood in which she lives as an adult. In
neither case do we ?nd a systematic link between having the “wrong” name and
the types of outcomes we are measuring.
26. Even if names have an impact that extends beyond the resume stage, in
an ef?cient market with suf?ciently many nondiscriminatory employers, the
presence of discrimination need not result in worse outcomes for Blacks [Becker
1957]. Note also that, at least in the past, a relatively small fraction of the jobs
were actually obtained through a formal resume-based process. Granovetter
 reports that approximately 10 percent of respondents in a survey report
obtaining their job through job advertisements.
27. From a legal perspective, the use of names as a basis for hiring decisions
is likely to be a violation of current law, regardless of whether there are underlying productivity differences. In the 1971 decision Griggs v. Duke Power, the
Supreme Court ruled unanimously that policies that are neutral on their face, but
have a disparate impact on Blacks are not allowed. This doctrine was codi?ed in
the Civil Rights Act of 1991 after the 1989 case Antonio v. Wards Cove Packing
modi?ed the Griggs ruling by stating that policies with disparate impacts were
allowable as long as they served a legitimate business interest. Indeed, even the
use of names to choose a subset of Blacks from an entirely Black hiring pool would
probably be viewed as illegal under Connecticut v. Teal, in which it was found that
even policies that have no disparate impact on a protected group, but harm some
individuals within that group, violate the law.
798 QUARTERLY JOURNAL OF ECONOMICSmight be correlated with labor productivity (see, e.g., Heckman
and Carneiro ), but are typically not included on a resume
(and are for the most part illegal for employers to inquire about):
whether a woman is a single mother, was born to a teenage
mother, was raised in a single-parent household, or the degree of
racial segregation into which she was born. The second dif?culty
in testing this hypothesis is that we do not have in our data all of
the information on a resume (e.g., particular schools attended,
complete work history, misspellings).
Our empirical strategy, in light of these shortcomings, is to
estimate a number of speci?cations in the general spirit of equation (2), varying the set of covariates included in the regression. A
critical difference between the earlier estimates and those presented below are that we now include information about the adult
circumstances of a woman as covariates, since such information is
on the resume. The results are presented in Table IV. Rows of the
table correspond to different factors that might be correlated with
labor productivity due to their in?uence on human capital: segregation in one’s birth hospital, mother’s marital status, whether
one’s mother was a teenager, the woman’s own birth weight, the
woman’s own marital status, the education level of the man who
is father to her children, and the total number of children born to
the woman. The ?rst two columns of the table include both Blacks
and Whites in the regressions. We do not, however, include race
dummies in the speci?cation because race is not directly observed
by the prospective employer from the resume. The third and
fourth columns of the table limit the sample only to Blacks. The
entries in the table are the coef?cient on the woman’s BNI. Each
table entry is from a different regression. The ?rst and third
columns do not include any covariates; the second and fourth
column includes the woman’s age, years of education, whether or
not she has private health insurance (the best measure we have
with respect to the quality of her current employment), zip code of
residence ?xed effects, and year dummies. These variables capture some of the information on a resume. Our sample is the set
of women whom we observe both at their birth in 1973–1974 and
as adults in 1989 –2000.
The results in Table IV suggest that a woman’s ?rst name is
indeed a useful predictor of the circumstances in which she grew
up and her current situation, both of which may in turn be
correlated with labor productivity. This is true even after including our crude set of controls that proxy for information available
on the resume. A woman’s name is a particularly important
DISTINCTIVELY BLACK NAMES 799predictor when we pool Blacks and Whites in the same regression
(columns 1 and 2). In column 2 a woman with a BNI equal to 100
(implying a name that no Whites have) is 20.9 percentage points
more likely to have been born to a teenage mother and 31.3
percentage points more likely to have been born out-of-wedlock
than a Black woman living in the same zip code with the same age
and education, but carrying a name that is equally common
among Whites and Blacks. The woman with a Black name is also
much more likely to have been born in a Black neighborhood, to
herself be unmarried, to have had lower birth weight, and to have
given birth to more children. The same pattern of results, although generally somewhat smaller in magnitude, is apparent
even when we restrict the sample to Blacks. In other words, even
if the employer knows that a candidate is Black, the Blackness of
THE SIGNALING VALUE OF NAMES TO EMPLOYERS
Sample includes Blacks
Sample includes only
on a resume
on a resume
Percent of Black babies in
woman’s birth hospital
0.3015 0.1417 0.0690 0.0526
(0.0026) (0.0045) (0.0064) (0.0085)
Woman born to a teenage
0.00260 0.00209 0.00238 0.00232
(0.00005) (0.00009) (0.00011) (0.00016)
Woman born to an unmarried
0.00508 0.00313 0.00193 0.00176
(0.00005) (0.00009) (0.00011) (0.00017)
Woman’s birth weight
2.16 1.03 0.16 0.11
(0.07) (0.09) (0.13) (0.16)
Woman herself unmarried at
time she gives birth
0.00338 0.00111 0.00038 0.00023
(0.00006) (0.00006) (0.00010) (0.00009)
Years of education for the
man who fathers the
0.0050 0.0002 0.0010 0.0006
(0.0003) (0.0004) (0.0006) (0.0006)
Total number of children
born to the woman
0.00283 0.00238 0.00079 0.00090
(0.00011) (0.00016) (0.00025) (0.00029)
The relevant dependent variable is listed on the left-hand side of the table. The values reported in the
table are the coef?cients on the Black Name Index of the woman. Each table entry is from a separate
regression. In columns 1 and 3, no controls are included. In columns 2 and 4, controls for a woman’s age, years
of education, zip code of residence, whether the woman is privately insured, and year dummies are included.
These variables proxy for some of the types of information available to employers on resumes. The sample
used in all regressions is the set of black women for whom we successfully link information from their own
birth certi?cate to their child’s birth certi?cate. Unlike earlier regressions, these speci?cations control for
choices that a woman makes over the course of her life, such as years of education. The number of
observations is 62,309 for the sample that includes Blacks and Whites and 18,427 for the sample that only
800 QUARTERLY JOURNAL OF ECONOMICSthe name continues to serve as an important signal of socioeconomic status. Thus, while we cannot rule out animus on the part
of employers, we ?nd evidence supporting a potential productivity-related statistical discrimination motive for employers to base
interview decisions on ?rst names.
We document stark differences in naming patterns between
Blacks and Whites, and demonstrate that these patterns change
sharply over time. While most Blacks have shifted toward more
distinctively Black names (particularly in the late 1960s and
early 1970s), the fraction of Blacks choosing starkly White names
has also increased. How distinctively Black one’s name was appears to have signaled little in the early 1960s. Naming conventions differed modestly across parental characteristics or neighborhood types. The last two decades, however, have led to a
“ghettoization” of distinctively Black names, namely, a distinctively Black name is now a much stronger predictor of socioeconomic status. Among the theories we consider, models in which
the rise of the Black Power movement triggers important changes
in Black identity appear to be most consistent with our data. We
?nd no relationship between how Black one’s name is and life
outcomes after controlling for other factors. If that conclusion is
correct, then the proper interpretation of earlier audit studies
using Black names on resumes is either that the impact of names
does not extend beyond the callback decision (because race is
directly observed at the interview stage), or that names are correlated with determinants of productivity not captured by a resume. In our data, it is dif?cult to distinguish between these
More generally, this paper takes ?rst steps toward an attempt to understand what role Black culture might play in explaining continued poverty and racial isolation. With respect to
this particular aspect of distinctive Black culture, we conclude
that carrying a black name is primarily a consequence rather than
a cause of poverty and segregation.
APPENDIX: DATA DESCRIPTION
In this data appendix we describe the data sources that we
draw upon in our analysis, give a description of some data limiDISTINCTIVELY BLACK NAMES 801tations and other data issues with which we are confronted,
provide de?nitions, and describe the process used to link mothers.
1. Data Sources
Birth Data: Our empirical analyses are mainly based on data
drawn from the Birth Statistical Master File maintained by the
Of?ce of Vital Records in the California Department of Health
Services. These ?les provide information drawn from birth certi?cates for virtually all children born in California over the
period 1961–2000. With the approval of the California Committee
for the Protection of Human Subjects, we have been able to
supplement the information contained on the public use versions
of these data sets with personal identi?ers including mother’s
?rst name, mother’s maiden name, and child’s full name.
Zip Code Statistics: U. S. Bureau of the Census, American
Fact Finder, 1990 Census.
Demographic and Socioeconomic Data: For an accuracy
check on mother-children links, data were obtained from the
American Community Survey 5 Percent Public Use of Microdata
Samples (PUMS) for California and United States (All States),
U. S. Bureau of the Census Arabic First Names: To identify and
discard Arabic names from our data, we used Bruce Lansky
, Baby Names Around the World.
2. Data Limitations and Other Data Issues
Race/Ethnicity: From 1998 to 2000, information of a child’s
race is missing. For these three years, a child is considered Black
if either parent is Black. In other years, over 98 percent of
children with at least one Black parent are coded as Black. Prior
to 1982, most Hispanics are included with whites, and it is not
possible to directly calculate statistics for Non-Hispanics. Beginning in 1982, an identi?er for Hispanic ethnicity was added to the
birth certi?cate in California. Using information from this latter
period, we drop anyone in the earlier time period with a surname
or mother’s maiden name that is more than 10 percent Hispanic.
Link of Birth Certi?cate Data for Women Born in 1973–1974
to When They Give Birth Themselves in the Period 1989 –2000: In
order to uniquely link information from a woman’s own birth
certi?cate to those of her children when she gives birth, a woman
must both be born in California and later give birth there. Only
after 1989 do we have the mother’s date of birth and full ?rst
name, two critical pieces of information for making the linkage.
We thus limit the sample to babies born 1989 –2000 to Black
women themselves born in California. In order to identify women
802 QUARTERLY JOURNAL OF ECONOMICSwhose birth histories are likely to be most fully captured by the
period 1989 –2000, we restrict the matching to women who were
themselves born in 1973–1974. We restrict the sample to Black
women born in California. We then carry out ?ve different matching procedures in which we use a mother’s exact date of birth and
permutations of her ?rst name and maiden name (match only on
maiden name, only on ?rst name, on ?rst name and maiden
name, on ?rst initial and maiden name, and on ?rst name and
maiden name initial). We keep only cases where the match between mother and child is unique; i.e., there is no other woman
born in California in 1973–1974 who has information that could
possibly match the characteristics of the mother on the birth
certi?cate. Because of typographical errors, using only a subset of
the information in a woman’s name somewhat increases the
number of successful matches.
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