a genome-wide search for quantitative trait loci influencing substance dependence vulnerability in...
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A genome-wide search for quantitative trait loci influencing substancedependence vulnerability in adolescence
Michael C. Stallings a,*, Robin P. Corley a, John K. Hewitt a, Kenneth S. Krauter b,Jeffrey M. Lessem a, Susan K. Mikulich c, Soo Hyun Rhee a, Andrew Smolen a,
Susan E. Young a, Thomas J. Crowley c
a Institute for Behavioral Genetics, University of Colorado, Campus Box 447, Boulder, CO 80309-0447, USAb Molecular, Cellular and Developmental Biology, University of Colorado, Boulder, CO 80309, USA
c Division of Substance Dependence, University of Colorado School of Medicine, Denver, CO 80262, USA
Received 16 September 2002; received in revised form 6 January 2003; accepted 7 January 2003
Abstract
This study describes results from a genome-wide search for quantitative trait loci (QTL) influencing substance dependence
vulnerability in adolescence. We utilized regression-based multipoint (and single-point) QTL mapping procedures designed for
selected sibpair samples. Selected sibling pairs included 250 proband-sibling pairs from 192 families. Clinical probands (13�/19 years
of age) were drawn from consecutive admissions to substance abuse treatment facilities in the Denver metropolitan area; siblings of
probands ranged in age from 12 to 25 years. In addition to the selected sample, a community-based sample of 3676 adolescents and
young adults were utilized to define a clinically-significant, heritable, age- and sex-normed index of substance dependence
vulnerability*/a priori and independent of our linkage results. Siblings and their parents were genotyped for 374 STR micro-
satellite markers distributed across the 22 autosomes (average inter-marker distance�/9.2 cM). Non-parametric single-point linkage
results indicated 17 markers on 11 chromosomes with nominally significant tests of linkage; six markers with LOD scores greater
than 1.0 and one marker (D3S1614) with a LOD score of 2.2. Multipoint mapping corroborated two locations and provided
preliminary evidence for linkage to regions on chromosome 3q24-25 (near markers D3S1279 and D3S1614) and chromosome 9q34
(near markers D9S1826 and D9S1838).
# 2003 Elsevier Science Ireland Ltd. All rights reserved.
Keywords: Genetics; Substance dependence vulnerability; Adolescence; Linkage study
1. Introduction
We present findings from the first genome-wide scan
for quantitative trait loci (QTL) influencing substance
dependence vulnerability in adolescence. Psychoactive
substance dependence is the most highly familial psy-
chiatric disorder (DSM-IV; American Psychiatric Asso-
ciation, 1994). The essential features of the disorder
include a cluster of cognitive, behavioral, and physiolo-
gical symptoms indicating tolerance and withdrawal,
impaired control of substance use, and continued use
despite adverse consequences.
Evidence suggests that substance dependence is a
multifactorial, complex disorder, likely to be influenced
by multiple genetic and environmental factors. Findings
from family, twin, and adoption studies strongly suggest
that genetic determinants play an important role in
patterns of drinking behavior and in the etiology of
alcoholism (Cotton, 1979; Goodwin, 1979, 1985; Heath
et al., 1997, 2001, 1991; Hrubec and Omenn, 1981;
McGue et al., 2001; Prescott et al., 1994; Prescott and
Kendler, 1999; Prescott et al., 1997; Robins, 1996; Rose
et al., 2001; Schuckit, 1987, 1994, 1999), with children of
alcoholics tending to show a 3- to 5-fold increased risk
for developing the disorder (Cloninger et al., 1981;
Cotton, 1979; Schuckit, 1999). Heritability estimates
from twin studies for smoking behaviors are also
substantial (in the range of 40�/50%; for a review see
* Corresponding author. Tel.: �/1-303-492-2826; fax: �/1-303-492-
8063.
E-mail address: [email protected] (M.C. Stallings).
Drug and Alcohol Dependence 70 (2003) 295�/307
www.elsevier.com/locate/drugalcdep
03765-8716/03/$ - see front matter # 2003 Elsevier Science Ireland Ltd. All rights reserved.
doi:10.1016/S0376-8716(03)00031-0
(Heath and Madden, 1995), and recent studies have
confirmed substantial heritable influences on smoking
initiation (Rhee et al., in review), quantity of cigarettes
smoked (Koopmans et al., 1999), persistent smoking(True et al., 1997) and nicotine dependence (McGue et
al., 2000; True et al., 1999).
Studies specifically investigating the etiology of illicit
drug abuse and dependence are less abundant than for
smoking and problem drinking, but the findings, in
general, suggest important genetic and familial contri-
butions to illicit drug use and the development of illicit
substance use disorders as well (Annis, 1974; Gfroerer,1987; Han et al., 1999; Kendler et al., 2000; Kendler and
Prescott, 1998; Luthar and Rounsaville, 1993; Maddux
and Desmond, 1989; Maes et al., 1999; McGue et al.,
2000; Merikangas and Avenevoli, 2000; Moss et al.,
1994; Newlin et al., 2000; Rounsaville et al., 1991;
Tsuang et al., 1996, 1998).
Although it is generally well accepted that genetic
influences play a significant role in substance depen-dence vulnerability, the specific mechanisms by which
genetic factors exert their influence remain unknown.
Two important approaches to investigating potential
mechanisms have included: (1) understanding individual
differences in physiological and pharmacogenetic vul-
nerabilities to specific classes of substances (e.g. Chen et
al., 2002; Higuchi, 1994; Kreek, 2000; Reich et al., 1998;
Schuckit et al., 2001; Stitzel et al., 2000; Straub et al.,1999); and (2) investigating individual differences in
non-specific substance dependence vulnerability*/po-
tentially as part of a spectrum of risk behaviors related
to the inability to inhibit inappropriate behavior in
general (Babor et al., 1992; Cadoret et al., 1995;
Cloninger, 1987; Cloninger et al., 1981, 1988; Hessel-
brock et al., 1992; Iacono et al., 1999; Jessor et al., 1991;
Krueger et al., 2002; Moffitt, 1993; Sher and Trull, 1994;Young et al., 2000).
1.1. The present study
In this report we focus on non-specific substance
dependence vulnerability for several reasons. First, most
individuals with a substance use disorder (SUD) use
multiple substances (Glantz and Leshner, 2000), and
polysubstance use is particularly characteristic of ado-lescents (Johnston et al., 2001; Young et al., 2002).
Second, although the conclusions drawn from family
and twin studies examining the causes of comorbidity
among substance use disorders have been conflicting,
there is considerable support for the existence of
important common genetic or common familial influ-
ences across multiple substances (Bierut et al., 1998;
Cadoret et al., 1986, 1995; Kendler et al., 1997; True etal., 1999; Tsuang et al., 1998). Other studies have
stressed the importance of substance-specific familial
influences (Meller et al., 1988; Merikangas et al., 1998),
however, there is accumulating evidence to suggest that,
especially in adolescence, underlying genetic risk factors
are likely to have general influences on vulnerability to
substance dependence, and possibly externalizing beha-vior as well (Krueger et al., 2002; Slutske et al., 1998;
Young et al., 2000). Consequently, composite pheno-
types that assess non-specific substance dependence
vulnerability may index the effects of genetic influences
better than measures of substance-specific problem use
in adolescence.
2. Methods
2.1. Study samples
All subjects are participants in the family, twin, and
adoption studies of our Colorado Center on Antisocial
Drug Dependence (CADD; PI: Thomas J. Crowley)
funded by the National Institute on Drug Abuse.
2.1.1. Ascertainment of selected sibpair sample
Adolescent treatment probands were recruited from
three treatment facilities (one residential and two out-
patient facilities) in the Denver metropolitan area
operated by the Division of Substance Dependence of
the University of Colorado School of Medicine. The
probands were 13�/19 years of age (M�/15.9, S.D.�/
1.3) at time of assessment*/with most referred intotreatment by social service and/or juvenile justice
agencies for serious substance involvement and delin-
quency (ca. 1% are referred by parents or other sources).
Proband participants were drawn from consecutive
admissions to the treatment facilities between February
1993 and June 2001. Exclusionary criteria included
imminent danger to self or others, current psychotic
symptoms, or IQ scores B/80. Only probands with abiological full-sibling between the ages of 12 and 25 (ca.
60% of admissions) were utilized in the current study.
The resulting selected sibpair sample included 250
proband-sibling pairs from 192 families (after omission
of 24 individuals where paternity and/or full-sibling
status was questioned based on genetic analysis). The
self-reported ethnicity distribution of the 192 families
was 7.8% African-American, 36.5% Hispanic, 52.1%Caucasian, and 3.6% other.
2.1.2. Ascertainment of community samples
In addition to the selected proband-sibling sample, we
used data from unselected adolescent and young adult
participants in the CADD family, twin, and adoption
samples (N�/3676 individuals between the ages of 12
and 25) to assist with phenotype definition. Monozygo-tic (N�/322 pairs) and dizygotic (N�/294 pairs) twins
and their non-twin siblings were drawn from the Color-
ado Twin Registry, a community-based sample of twin
M.C. Stallings et al. / Drug and Alcohol Dependence 70 (2003) 295�/307296
families residing in Colorado. Adolescents and young
adults were also drawn from two other Colorado
community-based family samples: the Colorado Adop-
tion Project (CAP) and the Colorado Adolescent Sub-stance Abuse (ASA) family study. The CAP is an
ongoing, longitudinal study of the genetic and environ-
mental influences on behavioral, cognitive, and emo-
tional development (DeFries et al., 1994). Our
community-based sample included 143 CAP adoptive
sibling pairs and 162 full sibling pairs from the matched
community families in the CAP. The ASA project is a
study of the familial transmission of substance abuseand associated psychopathology. The study design
includes families of adolescents in treatment for sub-
stance abuse and delinquency (described above) and the
families of unselected control adolescents age- and
ethnically-matched to the treatment probands. The
matched ASA control adolescents and their siblings
included 475 sibling pairs in the adolescent and young
adult age range.The complete community sample ranged in age from
12 to 25 years (M�/15.9; S.D.�/2.1) and was 54%
female (46% male). The ethnicity distribution of the
community sample was 81.6% Caucasian, 12.1% His-
panic, 2.3% African-American, with 4% of mixed or
unknown ethnicity. A recent report on this sample by
Young et al. (2002) has demonstrated that substance use
patterns and prevalence rates in our combined commu-nity sample are comparable to those reported in
national studies such as the Monitoring the Future
Study (Johnston et al., 2000; Johnston et al., 2001) and
the National Household Survey of Drug Abuse
(SAMHSA, 2001).
2.2. Assessment
All study participants were given an extensive batteryof cognitive, psychiatric, and socio-demographic assess-
ments that included both structured diagnostic inter-
views as well as self-report pencil-and-paper
questionnaires. Treatment probands were assessed in
the treatment facilities at time of admission. Siblings of
the treatment probands and all community adolescents
were assessed privately in their homes by trained lay
interviewers. All participants who were at least 18 yearsof age gave informed written consent to participate. For
juveniles, a parent or legal guardian gave written
consent for participation and written assent was ob-
tained from all juveniles. All research protocols and
consent forms were approved by institutional review
boards of the University of Colorado. All subjects were
paid for participation in the study.
Substance use data were obtained using the Compo-site International Diagnostic Interview-Substance
Abuse Module (CIDI-SAM; Cottler and Keating,
1990), a face-to-face structured diagnostic interview
designed to be administered by lay interviewers. The
CIDI-SAM has been shown to be valid and reliable in
both clinical and epidemiological samples (Cottler and
Keating, 1990; Horton et al., 2000), and in adolescentpopulations (Crowley et al., 2001). The structured
interview assesses substance use patterns and DSM-IV
(American Psychiatric Association, 1994) symptoms and
diagnoses of substance abuse and dependence for
tobacco, alcohol, and eight classes of illicit drugs. In
order to be asked follow-up questions regarding abuse
and dependence symptoms, subjects must report having
‘repeated use’, which was defined as using tobacco‘almost every day for at least a month’, consuming six
or more alcoholic drinks (lifetime), or using an illicit
drug (e.g. marijuana) six or more times (lifetime).
2.3. Phenotype definition
Ten candidate phenotypes were examined in our
community samples to identify (a priori and indepen-
dent of our linkage results) a phenotype to index non-specific dependence vulnerability. We desired a pheno-
type that: (1) was highly heritable in our community-
based samples; (2) showed a pattern of mean differences
in our clinical families that was consistent with strong
genetic transmission; (3) was not substantially influ-
enced by shared environmental factors; and (4) signifi-
cantly discriminated patients with substance use
disorders from community controls.Given our adolescent samples it was necessary to
consider age trends in substance dependence in our
community samples. Our data indicate a marked, almost
linear, increase in the number of substance dependence
symptoms (DSM-IV criterion counts) across the ado-
lescent age range 12�/18 (Young et al., 2002). Sex
differences in these trends were generally modest. To
adjust for age and sex effects, dependence symptomcounts were age- and sex-corrected using standard
regression procedures (i.e. residual scores were obtained)
and then standardized within sex groups to express
dependence vulnerability in relation to the population
averages and variability for adolescent males and
females.
Since there is no standard method for assessing
substance dependence vulnerability in adolescents weconsidered ten candidate phenotypes for this study. The
twin and non-twin sibling correlations for each index
from our community adolescent samples are shown in
Table 1. Comparisons of the sibling correlations and
biometrical model fitting (Corley et al., 2001) suggested
that the average number of dependence symptoms (i.e.
total symptom count across all classes of substances,
divided by the number of substances used more than fivetimes*/as defined by the CIDI-SAM) would provide the
best phenotype for use in our sibpair linkage analyses.
The sibling correlations for this phenotype show: (1) the
M.C. Stallings et al. / Drug and Alcohol Dependence 70 (2003) 295�/307 297
greatest discrepancy between MZ and DZ twins*/
indicating that it was the most highly heritable pheno-
type; (2) the least variation between DZ twins and full-
siblings from the ASA and CAP samples*/which can
differ only because of non-genetic factors; and (3) the
lowest correlation among adoptive siblings*/indicating
that it was one of the candidate phenotypes least
influenced by shared environmental effects. No other
candidate phenotype met all three of these criteria.
The heritability of this index of dependence vulner-
ability, also similarly age- and sex-corrected, was
estimated at 48% while shared environmental influences
explained only approximately 10% of the variance. The
average number of dependence symptoms per substance
used repeatedly also significantly discriminated (i.e.
demonstrated substantial mean differences) between
clinical probands (M�/2.19, S.D.�/1.41) and commu-
nity adolescents (M�/0.0 and S.D.�/1.0 due to stan-
dardization on our community adolescent sample). That
is, on average, clinical probands scored more than two
S.D. above the mean of unselected community adoles-
cents. This dependence vulnerability index also showed
a characteristic decreasing pattern of mean differences
across the clinical probands, full-siblings (M�/0.52,
S.D.�/1.35), and half-siblings (M�/0.32, S.D.�/1.34)
in our treatment families*/consistent with substantial
genetic influence.
2.4. DNA collection, preamplification, and genotyping
Genomic DNA was isolated from buccal cells using a
modification of published procedures (Freeman et al.,
1997; Lench et al., 1988; Meulenbelt et al., 1995).
Briefly, our method involved collecting buccal cells by
rubbing the cheeks with cotton swabs followed by a
rinse with Scope† mouthwash. The DNA was isolated
by solvent extraction, quantified with PicoGreen†
(Molecular Probes, Eugene, OR), and a working stock
of 20 ng/ul was prepared in TE buffer. The average yield
of DNA was 409/5 ug. Primer Extension Preamplifica-
tion (PEP) was performed on 1 ml aliqouts of the
genomic DNA using a modification (Krauter et al.,
2001) of the method of Zhang et al. (1992), which
resulted in an approximately 100-fold amplification of
the DNA. The PEP procedure was originally to be used
only on those few samples that had poor yields.
However, after confirming that allele calls for all
markers were identical when comparing PEP DNA
with DNA purified from cell lines in two CEPH
individuals (Krauter et al., 2001), PEP was routinely
used for all of the DNA samples.
Available parents and all sibling pairs from our
selected families (families of clinical probands) were
genotyped for 374 STR microsatellite markers (ABI
PRISM LMS2-MD10 panels, PE-Biosystems, Foster
City, CA) spanning all 22 autosomes. For 47% of the
Table 1
Sibling resemblance for ten candidate phenotypes indexing substance dependence vulnerability
Candidate phenotypes MZ twins
(N a�/322)
DZ twins
(N�/294)
ASA full-sibs
(N�/475)
CAP full-sibs
(N�/162)
CAP adop-sibs
(N�/143)
Total number of symptomsb, all substances 0.78 0.60 0.33 0.37 0.26
Total number of symptoms, excluding tob 0.74 0.64 0.34 0.27 0.19
Total number of symptoms, excluding alc and tob 0.69 0.80 0.38 0.28 0.23
Averagec number of symptoms, all substances 0.67 0.43 0.26 0.33 0.16
Average number of symptoms, excluding tob 0.65 0.48 0.26 0.26 0.19
Average number of symptoms, excluding
alc and tob
0.63 0.73 0.33 0.28 0.24
Marijuana symptoms only 0.62 0.73 0.34 0.29 0.25
Number of substances with at least one symptom 0.66 0.51 0.34 0.33 0.16
Number of substance dependence diagnoses 0.76 0.81 0.28 0.16 0.25
Number of symptoms for at least one substanced 0.67 0.56 0.32 0.30 0.18
a N , number of pairs.b Total number of symptoms�/the total number of DSM-IV substance dependence criteria endorsed combined across all ten substance categories
of the CIDI-SAM.c Average�/total number of symptoms divided by the number of substances used repeatedly*/as defined by the CIDI-SAM.d Number of symptoms for at least one substance�/the total number of DSM-IV criteria endorsed, but the same criterion endorsed across
multiple substances was counted only once (i.e. the total range was zero to seven symptoms).
M.C. Stallings et al. / Drug and Alcohol Dependence 70 (2003) 295�/307298
families genotypes were available from both parents;
49% included genotypes from one parent and for 4% of
the sibships no parental genotypes were available.
Sibships included 147 pairs, 35 trios, seven sibships offour, and three sibships of five. Genotypes were
determined by PCR amplification of polymorphic loci
using primers labeled with fluorescent probes. DNA
fragments were analyzed using an ABI 377 DNA
sequencing instrument and GENESCAN and GENOTYPER
software. Allele calling was performed by technicians
blind to subject identity and phenotype. Sex-averaged
marker maps were obtained from the Marshfield Centerfor Medical Genetics database (http://research.marsh-
fieldclinic.org/genetics), and allele frequencies were esti-
mated from the full sample. The average inter-marker
distance across the 22 autosomes was approximately
9.24 cM, with an average marker heterozygosity of
78.29% and average polymorphism information content
(PIC) of 0.55.
2.5. Validation of genotypes and relationship status
The Discovery Manager† (Genomica; Boulder, CO)
database system was used for storage of genetic (raw
allele sizes) and phenotypic data, and for initial error
checking. Additional relationship and genotype valida-
tion was performed using the Graphical Relationship
Representation (GRR) program (Abecasis et al., 2001),
PEDSTATS (Abecasis et al., 2000), MERLIN (Abecasis etal., 2002), and GENEHUNTER version 2.0 (Kruglyak et
al., 1996). Identity-by-descent (IBD) sharing for all
sibpairs was estimated at 1 cM intervals (and also
single-point at each marker) across the genome (auto-
somes) using MERLIN. GRR was used to confirm the
putative family pedigree relationships in the final
sample. This software provides a graphical plot of the
average identity-by-state (IBS) by the S.D. of IBS for allavailable markers for all pairs of individuals. Analysis
indicated 24 individuals where paternity and/or full-
sibling status was questioned and two pairs of mono-
zygotic twins. These individuals were removed from the
final sample prior to linkage analysis. Comparison of
allele calls in the two pairs of identical twins indicated
that our undetectable genotyping error rate is less than
1%.
2.6. Data analysis
The regression-based sibpair linkage analysis that we
utilized was proposed by Fulker and colleagues (Fulker
and Cardon, 1994; Fulker et al., 1991) as an extension of
the methods originally developed by DeFries and Fulker
(1985, 1988) for the analysis of selected twin data. Therationale of the DeFries�/Fulker (DF) linkage analysis
for selected sibling samples is that the siblings of selected
(clinical) probands should demonstrate differential re-
gression toward the unselected (population) mean on a
quantitative trait (e.g. our index of dependence vulner-
ability), commensurate with the proportion of marker
alleles they share IBD with the proband*/given that aquantitative trait locus (QTL) is linked to a given
chromosomal marker.
The following regression model was fit to data from
250 proband-sibling pairs:
C�a�b1P�b2(pi)�o
where C is the quantitative score of the co-sibling of a
selected (clinical) proband, P is the proband’s score, pi
is the estimated average proportion of alleles sharedIBD for the sibling pair at location (i ), and a and o are
the regression constant and disturbance term, respec-
tively. A t-test of the significance of the b2 regression
coefficient (t�/b2/Seb2) provides a test of linkage, which
can be expressed as an approximate LOD score (t2/
4.6:/LOD score). We used the DF regression-based
QTL linkage analysis as operationalized in QMS2
(Lessem and Cherny, 2001), a series of integratedSAS# macros (SAS, 2000) available at: http://ibgwww.-
colorado.edu/�/lessem/software/qms2.html.
3. Results
3.1. Descriptive results
The percentage of subjects in our clinical and com-munity samples meeting DSM-IV criteria for a diagnosis
of substance dependence are presented in Table 2.
Community control probands are adolescents matched
to the clinical probands by age, sex, ethnicity and
zipcode of residence. Note the substantially greater
prevalence of substance dependence in the clinical
probands and their siblings compared with community
adolescents. Prevalence rates also highlight the substan-
Table 2
Prevalence of substance dependence in our clinical and community
samples
Dependence diagnosisa Clinical Community
Probands Siblings Probandsb Siblings
Tobacco 56.3 26.5 8.3 9.0
Alcohol 36.0 9.4 5.7 4.0
Marijuana 59.9 14.4 5.1 6.7
Otherc 26.8 7.4 1.9 2.3
One or more diagnosis 78.6 33.5 14.0 13.0
Two or more diagnoses 56.7 14.4 4.4 6.2
Three or more diagnoses 34.8 8.2 1.9 1.7
a DSM-IV substance dependence diagnosis.b Community probands, adolescents matched to the clinical pro-
bands by age (9/1 year), sex, ethnicity and zipcode of residence.c Other, illicit substance other than marijuana.
M.C. Stallings et al. / Drug and Alcohol Dependence 70 (2003) 295�/307 299
tial polysubstance use among adolescents in treatment
for substance use disorders, with over half of the clinical
probands meeting criteria for two or more substance
dependence diagnoses and about one third meetingcriteria for three or more diagnoses. Siblings of the
clinical probands also show substantially higher rates of
substance dependence and dependence on multiple
substances than community adolescents. These data
underscore the necessity of utilizing a composite index
of dependence vulnerability in our adolescent samples.
3.2. Single-point linkage results
Table 3 shows chromosomal markers where single-
point DF regression analyses resulted in a significant t-
value (P B/0.05). Reported P -values are actual values
obtained without adjustment for multiple testing. Re-
sults indicated 17 nominally significant single-point
results on 11 chromosomes: 2, 3q, 4q, 6q, 7q, 9q, 11p,13q, 18q, 19q and 20. For six marker locations (located
on chromosomes 3q24-25, 9q34, 11p15, 20p11 and
20q11) LOD scores exceeded 1.0. At marker D3S1614
on chromosome 3q25, a single-point LOD score of 2.24
was obtained.
3.3. Multipoint results
Fig. 1 shows LOD score plots from multipoint DF
regression analyses performed at 1 cM intervals across
the genome (22 autosomes). Cumulative distance in
Haldane cM is shown along the bottom of the figure and
the corresponding chromosome numbers are shown at
the top of Fig. 1. Multipoint mapping results corrobo-
rated our single-point linkage results for two locations,
and suggested potential QTL on chromosome 3q (in the
vicinity of markers D3S1279 and D3S1614), and near
the telomere of chromosome 9q (in the vicinity of
makers D9S1826 and D9S1838). The two peak LOD
score locations (LOD�/1.5) on chromosome 3q24-25
(LOD�/1.60) and chromosome 9q34 (LOD�/1.92) are
shown in greater detail in Figs. 2 and 3. Descriptive
statistics from our DF regression analyses at these two
locations are presented in Table 4.
An important assumption of the regression-based
methods that we employed is that the residuals (i.e.
differences between observed and predicted scores) are
normally and equally distributed across levels of the
independent variable (estimated multipoint IBD). Plots
of residuals revealed no obvious violations of this
assumption and evaluation of regression influence
statistics indicated no particularly influential cases or
outliers. Co-sibling means were plotted as a function of
the estimated average number of alleles shared IBD with
the clinical probands for the peak locations on chromo-
some 3q24-25 and chromosome 9q34. To compute the
co-sibling means we collapsed the estimated IBD
distribution into three categories based on the following
intervals: 0�/25; �/25�/75; and �/75% alleles shared IBD
at each location. The co-sibling means for dependence
vulnerability showed an approximate linear increase in
relation to the proportion of alleles shared IBD with the
proband at both peak locations. These data suggested a
mean difference of approximately one-half a S.D. on
our dependence vulnerability index between sibpairs
with an estimated IBD of less than 0.25 at the peak
Table 3
Single-point linkage results
Chromosome Marker Positiona t b P Infoc LOD
2 D2S319 7.60 1.87 0.03 0.42 0.76
2 D2S347 131.51 1.74 0.04 0.31 0.66
2 D2S338 250.54 1.89 0.03 0.36 0.78
3 D3S1279 169.60 2.50 0.01 0.50 1.36
3 D3S1614 177.75 3.21 0.01 0.42 2.24
4 D4S424 144.56 1.71 0.04 0.46 0.64
6 D6S446 189.00 1.66 0.05 0.37 0.60
7 D7S661 155.10 1.76 0.04 0.44 0.67
9 D9S1826 159.61 1.85 0.03 0.32 0.74
9 D9S1838 163.84 2.68 0.01 0.57 1.56
11 D11S902 21.47 2.32 0.01 0.30 1.17
13 D13S171 25.08 2.06 0.02 0.28 0.92
18 D18S478 52.86 1.82 0.04 0.37 0.72
19 D19S220 62.03 1.96 0.03 0.53 0.84
19 D19S420 66.30 1.71 0.04 0.51 0.64
20 D20S112 39.25 2.46 0.01 0.50 1.32
20 D20S107 55.74 2.26 0.01 0.42 1.11
a Position, distance in cM from the pterm.b t , test statistic from single-point DF regression analysis.c Info, single-point information at each marker; markers with single-point LOD scores greater than 1.0 are shown in bold face.
M.C. Stallings et al. / Drug and Alcohol Dependence 70 (2003) 295�/307300
locations, compared with sibling pairs with an estimated
IBD of greater than 0.75.
3.4. Qualitative analyses
Employing a variant of the affected sibpair method,
we defined affected status as scoring above a z -score
cutoff of 1.0 (and 1.96) on our dependence vulnerability
index. That is, sibling pairs were considered ‘affected’
sibpairs (i.e. extreme-scoring pairs) if they both scored
above the respective z-score cutoffs. When only the
proband exceeded the threshold and the co-sibling did
not, the pair was considered a discordant pair. Because
affection status is somewhat arbitrarily defined on the
quantitative trait, we used two definitions to define
affected sibpairs: a z -score greater than 1.0 would be
expected to include about 16% of the general popula-
tion; and a z-score greater than 1.96 would include
Fig. 1. Multipoint LOD scores Across the Genome. x -axis�/cumulative Haldane centimorgans (cM); y -axis�/multipoint LOD score estimated
from DF regression analyses; chromosome number is shown along the top of the figure.
Fig. 2. Multipoint results for chromosome 3. Chromosome 3 marker locations are shown along the x -axis; y -axis�/multipoint LOD score estimated
from DF regression analyses.
M.C. Stallings et al. / Drug and Alcohol Dependence 70 (2003) 295�/307 301
approximately 2.5% of the general population. Note,
however, that by defining affection status this way we
are not suggesting that many of our sibling pairs are
‘unaffected’ pairs. This was used simply to determine
whether sibling pairs concordant for extreme scores on
our quantitative index also showed increased allele
sharing IBD at the locations suggested by our regression
analyses.
Table 5 shows the estimated alleles shared IBD for
siblings defined as ‘affected’ and ‘discordant’ sibling
pairs for our peak locations, and for the flanking
markers proximal to each of the peak locations. We
found significantly greater allele sharing (63% vs. the
null expectation of 50%) only at marker D3S1279 on
chromosome 3q24 when affection status was defined as
a z -score greater than 1.96. However, the affected
sibpair sample sizes are relatively small, particularly
for our z-score cutoff of 1.96. In general, there is a trend
for increased allele sharing among extreme scoring
sibling pairs at both peak locations. Significantly
decreased allele sharing among discordant sibpairs was
found for all chromosome 9 locations for the more
extreme 1.96 threshold.
4. Discussion
The current study describes findings from our initial
autosome-wide search for QTL influencing substance
dependence vulnerability in adolescence. We utilized
non-parametric QTL mapping procedures designed for
selected sibling-pair samples (Fulker et al., 1991; Fulker
and Cardon, 1994). The sample included 250 proband-
sibling pairs from 192 families. Patient probands were
adolescents (13�/19 years of age) recruited from con-
secutive admissions to treatment facilities for severe
substance abuse and delinquency. Parents, and siblings
of the probands between the ages of 12 and 25, were also
recruited for participation. A quantitative phenotype,
indexing non-specific substance dependence vulnerabil-
ity was determined*/a priori and independent of our
linkage results*/utilizing structured interview data from
our clinical sample and a sample of 3676 unselected
adolescents and young adults. This quantitative pheno-
type (average number of dependence symptoms�/the
total number of dependence symptoms divided by the
number of substances used repeatedly), age- and sex-
normed on our community samples, was substantially
Fig. 3. Multipoint Results for Chromosome 9. Chromosome 9 marker locations are shown along the x -axis; y -axis�/multipoint LOD score
estimated from DF regression analyses.
Table 4
Multipoint results: peak chromosomal regions yielding LOD scores greater than 1.50
Chromosome Positiona (cM) Informationb t c P LOD
3q24-25 173 0.62 2.72 B/0.004 1.60
9q34 161 0.88 2.97 B/0.002 1.92
a Position, distance in cM from the pterm.b Information, multipoint information content at the position.c t , test statistic from multipoint DF regression analysis.
M.C. Stallings et al. / Drug and Alcohol Dependence 70 (2003) 295�/307302
heritable (h2�/0.48) and significantly discriminated
adolescent patient probands from unselected commu-
nity adolescents.
Multipoint mapping analyses suggested that the
strongest evidence for QTL influencing substance de-
pendence vulnerability was detected on chromosome
3q24-25 (in the vicinity of markers D3S1279 and
D3S1614) and chromosome 9q34 (in the vicinity of
markers D9S1826 and D9S1838). Although these loca-
tions do not meet criteria for significant linkage (see
Lander and Kruglyak, 1995), they are of sufficient
magnitude (LOD scores�/1.50) to provide a focus for
further study.
Both of these regions have been suggested in other
studies. Uhl et al. (2001), also investigating QTL for
polysubstance abuse vulnerability*/but utilizing adult
samples in a genome-wide association scan using a
pooled DNA strategy*/reported a significant associa-
tion to a region on chromosome 3 within 10 cM of our
peak location (173 cM from the pter). Long et al. (1998)
also reported suggestive evidence for linkage to three
markers on chromosome 3 spanning the region 165.3�/
181.1 cM in a genome scan for genetic linkage to alcohol
dependence. Bergen et al. (1999) report a similar region
associated with smoking status (ever vs. never smoked)
on chromosome 3 (171.7 cM), and also a region close to
our peak location on chromosome 9 (161 cM from the
pter).
A systematic search for genes within 15 cM of our
peak location on chromosome 3 (i.e. a 30 cM total
region) using the Golden Path Genome Browser (Kent
et al., 2002) from UCSC Human Genome Resources
(http://genome.ucsc.edu) yielded a total of 88 known or
suspected genes in the region. Although no candidate
genes previously associated with substance-related phe-
notypes are in this region, a number of potential
candidates (i.e. genes abundantly expressed in the brain
that may play important roles in neural developmentand/or signal transduction) include: the phospholipase
D1 gene (PLD1), a serine proteinase inhibitor gene
(SERPINI1), claudin 11 an oligodendrocyte transmem-
brane protein gene (CLDN11), and neuroligin 1
(NLGN1). Putative gene function was ascertained
from the GeneCards (Rebhan et al., 1997) database
(http://bioinformatics.weizman.ac.il/cards/).
A similar search of the region near our chromosome 9peak location yielded 91 known or suspected genes
within 15 cM of the 9q telomere. Again, putative gene
function was ascertained from GeneCards and candi-
dates were ranked in terms of their potential functional
significance. A potentially important candidate within
this region is the dopamine beta-hydroxylase gene
(DBH). However, when we added a SNP marker within
the DBH gene (DBH-1021C0/T; Zabetian et al., 2001)to our chromosome 9 map there was no evidence of
linkage to this marker suggesting our putative QTL is
distal to the DBH locus*/closer to the telomere. Other
potential candidates in the region include a neuroblas-
toma protein gene (AMY), a chloride intracellular
channel gene (CLIC3) and a calcium channel gene
(CACNA1B).
4.1. Limitations
Several limitations of the current study should be
noted that suggest some caution in interpreting our
results. A strength of our design was the use of a sample
of 250 selected sibling pairs which provides roughly the
same power as 1000�/2000 unselected sibling pairs
(Fulker and Cardon, 1994) utilizing our analytical
methods. Even so, the power to detect QTL of loweffect sizes (e.g. that account for less then 15% of the
phenotypic trait variance) is limited even in a highly
selected sample. Thus, it is possible that our findings
Table 5
Average allele sharing IBD at peak locations on C3 and C9 for affected and discordant sibpairs
Location Z a�/1.00 Z a�/1.96
Affectedb pairs (N�/58) Discordantc pairs (N�/128) Affectedb pairs (N�/31) Discordantc pairs (N�/109)
Chromosome 3q
D3S1279 0.57 0.48 0.63 0.48
D3S1614 0.59 0.52 0.58 0.51
Peak location 0.58 0.49 0.60 0.49
Chromosome 9q
D9S1826 0.53 0.45 0.58 0.42
D9S1838 0.54 0.44 0.59 0.41
Peak location 0.54 0.45 0.58 0.42
a Z , standardized score on quantitative index of substance dependence vulnerability.b Affected pairs, sibling pairs where both the proband and co-sibling both score above the respective z -score cutoff.c Discordant pairs, proband score is above threshold but co-sibling score is not; cell entries are the average percentage of alleles shared identical-
by-descent (from multipoint IBD probability estimates) at the respective locations; bold entries indicate significant deviations from the null
expectancy of 50%.
M.C. Stallings et al. / Drug and Alcohol Dependence 70 (2003) 295�/307 303
represent false positives, and replication in larger
adolescent samples is imperative. Substance use dis-
orders also develop over time. We used an age- and sex-
normed quantitative index of dependence vulnerabilityto address this. However, there remains some level of
uncertainty regarding the scores of adolescents and
young adults, particularly for our youngest subjects,
who have not fully passed through the age of risk. Our
measure of dependence vulnerability is most appropriate
for adolescents who have had experience with multiple
substances (i.e. it quantifies the extent to which indivi-
duals show dependence symptoms across a number ofsubstances that they have used repeatedly*/more than
five times as defined by the CIDI-SAM). Although
polysubstance use is characteristic of adolescent popula-
tions, and particularly our high risk probands and their
siblings, not all of our subjects have had experience with
multiple substances, and some have not used any
substances. Individuals who had never used any sub-
stances were scored zero on our vulnerability index,which may be a limitation of this phenotype for
adolescents in general. Further, the causes of adolescent
substance dependence are likely to include both general
and substance-specific risk factors. Our approach is very
unlikely to detect QTL that influence responses or
vulnerabilities to specific drugs. Instead, in this study
we have focused on attempting to identify QTL that
underlie general risk factors that may be shared acrossmultiple substances. A full understanding of the causes
of substance dependence will clearly require both
approaches. Finally, we should point out that our
clinical sample is selected for both problem substance
use and conduct disorder; thus, our findings may not
generalize to broader substance abusing populations.
In summary, we have performed the first genome scan
for QTL influencing substance dependence vulnerabilityin adolescence. Although our results do not indicate
significant evidence for linkage (see Lander and Kru-
glyak, 1995), few studies of comparable sample size will
individually have sufficient power to identify QTL at
this level of significance. An important strength of the
current study was our adherence to developing a
quantitative index of substance dependence vulnerabil-
ity in adolescence*/a priori and independent of ourlinkage results*/to minimize the inflation of Type-I
errors inherent in testing multiple phenotypes. Further,
although our results are preliminary, our strongest
evidence for linkage indicates two chromosomal regions
(3q24-25 and 9q34) also suggested by other recent
studies of substance-related phenotypes in adult popula-
tions (Bergen et al., 1999; Long et al., 1998; Uhl et al.,
2001).Ultimately, the identification of specific candidate
genes that contribute to substance dependence vulner-
ability in adolescence will improve our clinical under-
standing of substance use disorders in this population
and eventually lead to more accurate diagnosis and
effective treatments.
Acknowledgements
We want to especially thank the participants of the
clinical, family, twin, and adoption studies of the Center
for the Genetics and Treatment of Antisocial Drug
Dependence. Genotyping was conducted by Dr. Brianna
Dennehey, Liping Liu and Jane Hutchinson. We also
want to acknowledge Dr Stacey Cherny and Dr Marissa
Ehringer for statistical and bioinformatics consultation.This research was supported in part by NIDA grants
DA-05131, DA-11015, and DA-12845.
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