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EMPIRICAL RESEARCH
Age at Menarche and Adolescent Alcohol Use
Melissa Verhoef • Regina J. J. M. van den Eijnden •
Ina M. Koning • Wilma A. M. Vollebergh
Received: 3 September 2013 / Accepted: 2 December 2013
� Springer Science+Business Media New York 2013
Abstract Research has shown that early maturation is
related to problematic alcohol use, yet the differential
effect of early pubertal timing (i.e., younger age at men-
arche) on the onset of alcohol use and subsequent level of
alcohol use has rarely been examined. This distinction is
relevant, as younger age at menarche can have differential
effects on these outcomes, which in turn can have long-
lasting effects. Therefore, the present study examined the
relationship between age at menarche and adolescent
alcohol use among girls, hereby distinguishing between
onset and level of alcohol use. In addition, the moderating
effects of alcohol-specific rules, child disclosure and class
gender composition were examined. Participants were 430
girls from a Dutch four-wave survey, with a mean age of
12.17 years (SD = 0.50) at the beginning of the study.
Results showed that the probability of onset of alcohol use
was increased by younger age at menarche, but only when
girls were younger than 15. Moderation analyses showed
that younger age at menarche increased the risk of alcohol
onset only in low risk girls (with high levels of alcohol-
specific rules and in classes with a high percentage of
girls). Once adolescent girls started drinking alcohol,
younger age at menarche was associated positively with
alcohol consumption only for girls in classes with a mod-
erate to high percentage of girls. These findings confirm
that younger age at menarche is a risk factor for the onset
of alcohol use, but strongly suggest that this effect is
strongest for girls having restrictive alcohol-specific rules
and in classes with a high percentage of girls. Possibly, in
the absence of social factors that ‘‘push’’ to alcohol use,
biological factors (like age at menarche) become more
important. Another possibility is that adolescent girls start
drinking alcohol to oppose their parents if they set too strict
alcohol-specific rules.
Keywords Age at menarche � Adolescent alcohol use �Alcohol-specific rules � Child disclosure � Class gender
composition
Introduction
Younger age at menarche, a commonly used indicator for
early pubertal timing (Belsky et al. 2007), is shown to be
associated with a variety of problem behaviors, such as
alcohol use (Deardorff et al. 2005). The fact that this effect
of early pubertal timing persists into (young) adulthood
(Dick et al. 2000) underscores the significance of analyzing
the effect of early pubertal timing in more detail. The
current study adds to previous research by distinguishing
between the onset and level of alcohol use. This difference
is relevant, as earlier onset of alcohol use is associated with
more negative outcomes such as risky sexual behavior
(Boden and Fergusson 2011) or developing an alcohol-
related disorder (Stolle et al. 2009). In addition, by
examining several moderating variables, we aim to identify
those subgroups of adolescent girls that are at higher risk
for adolescent alcohol use.
Risk Factor for Adolescent Alcohol Use
Research has shown that early pubertal timing in girls is
associated with earlier onset of alcohol use (Deardorff et al.
2005), and higher alcohol use and heavy drinking
M. Verhoef (&) � R. J. J. M. van den Eijnden �I. M. Koning � W. A. M. Vollebergh
Faculty of Social and Behavioral Sciences, Utrecht University,
PO Box 80.140, 3508 TC Utrecht, The Netherlands
e-mail: [email protected]
123
J Youth Adolescence
DOI 10.1007/s10964-013-0075-6
Page 2
trajectories (Biehl et al. 2007), although several studies
only found significant results for a subsample of adoles-
cents. For example, Lynne-Landsman et al. (2010) only
found an effect for adolescents in high risk home envi-
ronments, with low levels of resources and high levels of
conflict being related to binge drinking. Heavy adolescent
alcohol use is problematic, as this is a risk factor for
multiple negative short- and long-term outcomes, such as
sexual assault, pregnancy, use of other substances and
traffic accidents (for a review, see Boden and Fergusson
2011). In addition, heavy alcohol use during adolescence is
associated with abnormalities in different areas of the brain
(Medina et al. 2008). The fact that these problem behaviors
continue into adulthood (Hayatbakhsh et al. 2008) under-
scores the significance of analyzing the effect of early
pubertal timing in more detail.
Several hypotheses have been put forward to explain the
effect of early pubertal timing on adolescent alcohol use.
According to the early-timing hypothesis (Stattin and
Magnusson 1990), early-maturing girls (i.e., girls with a
younger age at menarche) are particularly vulnerable to
adjustment difficulties in adolescence, because others
attribute greater maturity to them than warranted by their
chronological age, which is in contrast with their cognitive
and emotional levels of maturity. Consequently, early-
maturing girls may attempt to demonstrate maturity and
independence by displaying deviant behavior. One exam-
ple of such behavior is alcohol use during adolescence.
Drinking during this age period deviates from the basic
norms in society and can be considered as deviant (Goode
2010). Furthermore, adolescent alcohol use generates
negative reactions from others, in particular from parents
(Kristjansson et al. 2010), which also makes this behavior
deviant. In addition, it has been argued that adolescents
initiate or increase alcohol use because they want to display
independence to their parents and peers (Brody and Fore-
hand 1993). Thus, due to the desire of early-maturing girls
to display independence, it is expected that girls with a
younger age at menarche are at an increased risk of getting
involved in deviant behavior, such as alcohol use.
Previous studies investigating the association between
early pubertal timing and adolescent alcohol use rarely
distinguish between the onset and subsequent level of
alcohol use. One notable exception is the study of Costello
et al. (2007), who differentiate between alcohol use and
alcohol use disorder. Their results show that early matu-
ration is related significantly to alcohol use, but not to risk
of alcohol use disorder. However, as earlier onset of
alcohol use is related to more negative outcomes (Boden
and Fergusson 2011), examining the effect of earlier mat-
uration on onset of alcohol use is particularly interesting. It
can be argued that early pubertal timing is indeed of
importance in particular for the onset of alcohol use, as the
need to demonstrate maturity and independence, as
hypothesized by the early-timing hypothesis, decreases
over time (Stattin and Magnusson 1990). This is the case
because the gap between the chronological age and the
cognitive and emotional levels of maturity of early
maturing girls decreases when girls grow older. Therefore,
this study distinguishes between the onset and subsequent
level of adolescent alcohol use, making it possible to
examine whether the impact of early pubertal timing differs
for alcohol onset and subsequent drinking level. Yet, as
early pubertal timing has not constantly been found to be
associated to different graduations of alcohol use (e.g.,
Costello et al. 2007; Lanza and Collins 2002), it is
important to examine factors that contribute to the differ-
ential effect of pubertal timing on alcohol use, i.e.
moderators.
Contextual Amplification of the Effect of Early
Pubertal Timing
Since not every study found significant associations
between early pubertal timing and adolescent girls’ prob-
lem behavior, Ge and colleagues developed the contextual
amplification hypothesis to account for differential effects
of social and personal risk factors (Ge et al. 2011). This
hypothesis states that contextual factors moderate the
negative effects of early pubertal timing on problem
behaviors. Several of these contextual factors are addressed
in this study.
First, concerning the family environment, parenting
behavior is of interest. A lower level of parental monitoring
might give early-maturing girls the opportunity to associate
with older and/or deviant peers, which might lead to the
initiation of risk behaviors, including alcohol use (Westling
et al. 2008). It can be argued that the effect of alcohol-
specific parenting is stronger than that of general parenting
(Schelleman-Offermans et al. 2011), meaning that a lower
level of alcohol-specific rules set by parents might
strengthen the association between early pubertal timing
and adolescent alcohol use. Independent of early pubertal
timing, research has shown that adolescents with permis-
sive parents concerning adolescents’ alcohol use have an
increased risk of early adolescent drinking (Koning et al.
2010a) and heavy drinking trajectories (Van der Vorst et al.
2009). Alcohol-specific rules may work as a protective
factor against the negative association between early
pubertal timing and adolescent alcohol use. Consequently,
it is hypothesized that alcohol-specific rules moderate the
negative effect of younger age at menarche on adolescent
alcohol use.
A second important moderator within the family envi-
ronment is the extent to which the child provides infor-
mation to parents, i.e. children’s disclosure, as this might
J Youth Adolescence
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diminish the negative effects of early pubertal timing.
Fletcher et al. (2004) found that parental warmth and
control were positive predictors of perceived parental
knowledge. They argued that children with warm rela-
tionships with their parents are more likely to disclose
information about their personal domains to their parents.
In addition, child disclosure is found to be the primary
means by which parents obtain knowledge about their
children’s whereabouts and is related strongly to better
parent–child relationships (Kerr and Stattin 2000). Thus, a
child’s disclosure can be regarded as a proxy of family
support. It is hypothesized that low children’s disclosure
moderates the relationship between younger age at men-
arche and adolescent alcohol use, with low children’s
disclosure increasing the risk of alcohol use in early-
maturing girls. The relationship is hypothesized because
adolescent girls reporting high disclosure are expected to
have a lower need to demonstrate maturity and indepen-
dence, due to their better relationship with their parents.
Third, regarding school and peers, belonging to a same- or
mixed-sex group of peers influences the risk of deviant
behavior and psychological distress for girls. Prior studies have
shown that early-maturing girls in mixed-sex settings were
more involved in early substance use (Walls and Whitbeck
2011), delinquency (Caspi et al. 1993) and experienced more
psychological distress (Ge et al. 1996) than early-maturing girls
in all-girl settings. Previous research showed that early matu-
ration promotes affiliations with older boys (Caspi et al. 1993).
This may result in the initiation of a more mature lifestyle,
including experimentation with alcohol and tobacco (Stattin
and Magnusson 1990; Dick et al. 2000). In addition, Simmons
and Blyth (1987) have argued that early-maturing girls may
feel vulnerable due to sexual pressure exerted by older boys.
So, it seems that the gender composition or peer groups may
interact with the possible effects of age at menarche. Therefore,
it is hypothesized that there is a moderating effect of sex setting
on the relationship between younger age at menarche and
adolescent alcohol use, with early-maturing girls in classes with
a higher percentage of boys having an increased risk of alcohol
use in comparison with early-maturing girls in classes with a
higher percentage of girls.
These contextual moderators can also have differential
effects on the onset and subsequent level of adolescent
alcohol use. Based on the stronger hypothesized relation-
ship between early pubertal timing and the onset of
drinking (compared to level of alcohol use), we expect that
the contextual moderators also have a stronger effect on the
onset of adolescent alcohol use. So, we not only expect the
effects of early pubertal timing to be more pronounced in
adolescent girls with lower levels of alcohol-specific rules
and child disclosure, and in adolescent girls in classes with
a higher percentage of boys, but we also expect these
moderating effects to be stronger for the onset of
adolescent alcohol use, compared to the effect on the
drinking level of adolescents. The inclusion of these con-
textual factors is a notable contribution to the literature, as
this study appears to be one of the first to examine the
possible differential effects of risk factors on the onset as
well as the level of alcohol use, enabling us to examine the
effect of pubertal timing in more detail.
The Current Study
The primary aim of the present study is to examine the
relationship between younger age at menarche and ado-
lescent alcohol use in more detail by distinguishing the
onset of alcohol use and subsequent drinking level. Based
on previous research, it is expected that younger age at
menarche is of importance in particular for the onset of
alcohol use. In addition, moderating effects of this rela-
tionship by multiple psychosocial factors are examined,
with the expectation that the association between younger
age at menarche and adolescent alcohol use is stronger for
adolescent girls in high risk situations (with lower levels of
alcohol-specific rules and children’s disclosure, and in
classes with a higher percentage of boys). Moreover, we
expect that the moderating effects are stronger for onset of
alcohol use, compared with level of alcohol use.
Method
Design and Procedure
Data of this study are part of a longitudinal randomized clinical
trial called ‘‘Prevention of Alcohol Use in Students’’ (Koning
et al. 2009). Briefly, 80 randomly selected Dutch secondary
schools were invited by letter to participate in the study. Of the
invited schools, 19 were willing to participate. These schools
were randomly assigned to one of the three intervention con-
ditions, or to the control condition. For the present study, only
the female adolescents who were assigned to the control con-
dition were included. Data collection started at the beginning of
the first year in high school (T0; September/October 2006).
After 10 months, the first follow-up (T1) took place in May/
June 2007. The second follow-up (T2) was in May/June 2008
and the last wave (T3) in May/June 2009. Data collection took
place in the classroom, where digital questionnaires were
administered by trained research assistants.
Participants
Participants were 444 female adolescents, from four dif-
ferent schools. Due to initial non-response, either because
of their parents’ refusal or their absence from school on the
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day the questionnaire was administered, data of 14 girls
were missing. This resulted in 430 adolescent girls par-
ticipating in the first wave, with a mean age of 12.17 years
(range 11–14, SD = 0.50). The majority of the sample
(61.6 %) was enrolled in lower secondary vocational edu-
cation and 38.4 % was enrolled in higher general second-
ary and pre-university education. According to the Dutch
Central Bureau of Statistics, this division regarding edu-
cational level is representative for Dutch school-aged
adolescents (Dutch Central Bureau of Statistics 2006).
At the first follow-up, a total of 429 adolescent girls
(99.8 %) completed the follow-up measurement. At the sec-
ond and the third follow-up, there were respectively 379
(88.1 %) and 338 (78.6 %) adolescent girls still enrolled in
the study. Attrition analyses concerning alcohol use and
demographic variables showed firstly that adolescent girls
participating in every wave drank a lower average number of
alcoholic drinks per week at baseline (t(428) = 4.09,
p \ .001) than adolescent girls not participating in every
wave. Furthermore, participating adolescent girls were more
likely to be younger (t(428) = 3.08, p = .002) and were more
often in higher education (v2(1, N = 430) = 9.90, p = .002).
Measures
Alcohol Use
Adolescents’ alcohol use was measured using a quantity-
frequency measure, representing average weekly alcohol
use. Quantity was measured by asking girls how many
glasses of alcohol they usually drank on a weekday
(Monday to Thursday) and on a weekend day (Friday to
Sunday; Engels et al. 1999). Responses for weekdays
ranged from 0 to 11 or more glasses of alcohol, for
weekend days from 0 to 20 or more glasses of alcohol.
Frequency was measured by asking adolescent girls about
the number of days they usually drank alcohol, separately
for weekdays and weekend days (Engels and Knibbe
2000). Quantity-frequency was computed by calculating
the products of the number of glasses and the number of
days, after which the two products for week days and
weekend days were summed (Koning et al. 2011), the
maximum score being 104. A value of 1 or more indicates
that adolescent girls drank at least one glass of alcohol per
week. Onset of alcohol use was defined by dichotomizing
the continuous variable with ‘‘0’’ indicating girls who did
not drink alcohol and ‘‘1’’ indicating those who drank an
average of one or more glasses of alcohol per week.
Age at Menarche
Age at menarche was measured, at each wave, by asking
girls about onset of menarche (yes/no) and, if yes, their age
at first menarche (in year and months). Girls who respon-
ded in years only received the mean month value of girls of
the same age in years (Whincup et al. 2001). Previous
research showed that adolescent girls report their age at
menarche in a reliable and accurate way (Smolak et al.
2007). Still, to prevent any recall errors, we used infor-
mation from the first time girls reported age at menarche
(e.g., if onset of menarche occurred after the data collection
of wave 1, we used the information about age at menarche
from wave 2, not from wave 3). A higher value (age) on
this variable indicates that girls’ onset of menarche
occurred later.
Alcohol-Specific Rules
Alcohol-specific rules refer to the degree of restrictive rule-
setting by parents concerning alcohol use, as perceived by
the adolescent (Van der Vorst et al. 2005). Alcohol-specific
rules were measured by ten items (e.g., ‘‘I am allowed to
drink several glasses of alcohol when my parents are at
home’’ and ‘‘I am allowed to get tipsy when I am out with
friends’’). Items ranged from 1 (never) to 5 (always). These
items were reversely scored, with higher scores indicating
more restrictive rule-setting by parents. To obtain a total
score, the mean of the ten items was calculated, the max-
imum possible score being five. Cronbach’s alphas ranged
from .90 to .94 for the different waves.
Children’s Disclosure
Disclosure towards parents was measured using a five-item
questionnaire developed by Kerr and Stattin (2000; e.g.,
‘‘Do you tell your parents about school (how your courses
go, your relationships with teachers)?’’ and ‘‘Do you keep a
lot of secrets from your parents about what you do during
your free time?’’), ranging from 1 (never) to 5 (always).
Two items were reversely coded, to ensure that higher
scores are indicative of higher disclosure. Cronbach’s
alphas ranged from .71 to .76 for the different waves. For
the total score, the mean of the five items was computed,
the maximum possible score being five. As there were
barely any changes to the reported child disclosure between
the several time points, the mean over the four measure-
ments was used in the analyses.
Class Gender Composition
As for each respondent the gender was known, and each
respondent was assigned a class number, it was possible to
derive the gender distribution for each class at T0. Of this
gender distribution, the class gender composition was
computed, representing the percentage of girls in the class.
Each adolescent received a value, based on the percentage
J Youth Adolescence
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of girls in her class, the minimum possible score equals 0
and the maximum possible score equals 100. Classes in
Dutch secondary schools are differentiated by educational
level and, in addition, strongly organized by classrooms.
This means that students spend most of their school time
with the same peers who have a similar educational level.
Of course, contact with students from other classes at the
same grade (graduating class) is possible, but this is mostly
limited to recess, psychical education, and extracurricular
activities (De Bruyn and Cillessen 2006). Just as in the
majority of Western countries, classes in Dutch secondary
schools contain a mix of boys and girls (class gender
composition varied from 0.27 to 0.75). However, there are
some differences in school level, as there are more boys
enrolled in lower secondary vocational education and more
girls in higher general secondary and pre-university edu-
cation (Dutch Central Bureau of Statistics 2006).
Statistical Analyses
Descriptives were computed for the variables included in
the analyses. Both means and SD’s were computed for age
at menarche, the four alcohol quantity-frequency measures,
alcohol-specific rules, child disclosure and class gender
composition (%). In addition, Pearson correlations were
calculated to compute associations between these variables.
Next, onset of adolescent alcohol use was predicted using
separate hierarchical logistic multiple regressions, using
time-varying and time-invariant covariates. To predict onset
at T1, only the adolescent girls who did not start drinking on
T0 were selected. Age at menarche was entered in Step 1. In
Step 2, the time-varying covariate, alcohol-specific rules (at
T0), and the time-invariant covariates, child disclosure and
class gender composition were added. In Step 3, the inter-
actions between centered scores age at menarche and cen-
tered scores of the covariates were entered. These procedures
were repeated for onset of alcohol use at T2 and T3, hereby
using alcohol-specific rules at respectively T0, T1, and T2 as
time-varying covariates and selecting the adolescent girls
who did not start drinking at the previous time point.
Second, to predict the level of adolescent alcohol use, sep-
arate hierarchical linear multiple regressions were used, fol-
lowing the same procedure. For example, level of alcohol use at
T3 was only predicted for adolescent girls reporting alcohol use
at T2, using both time-varying and time-invariant covariates. In
the analyses concerning level of alcohol use, we controlled for
level of alcohol use of the previous time point(s). The model
used for the analyses is presented in Fig. 1.
For both moderation analyses, if an interaction proved to
be significant, simple slope analyses were conducted using
Hayes and Matthes’s (2009) MODPROBE approach. In
this way, regions in the range of the moderator variable can
be identified where the effect of the age at menarche on
adolescent alcohol use is statistically significant, following
the Johnson-Neyman technique. Missing values (varying
between 0.01 and 7.91 % of all values) were imputed using
expectation maximization (Acock 2005). To increase the
accuracy of imputing missing values, other items within the
same scale were used to predict the score of the missing
value. To reduce the influence of outliers (values [ 3 SD
from the mean), outlying cases (n = 15) were assigned the
value of the closest less extreme score (Tabachnick and
Fidell 2007). As we tested multiple models, we used the
Benjamini and Hochberg False Discovery Rate (Benjamini
and Yekutieli 2001) as correction method. All analyses
were performed using SPSS, version 20.0.
Results
Descriptives and Intercorrelations
Intercorrelations and descriptives are reported in Table 1. At
T0, 22.3 % of the adolescent girls had started drinking
Onset alcohol use T1a
Level alcohol use T1b
Onset alcohol use T2a
Level alcohol use T2bYounger age at menarche
Onset alcohol use T3a
Level alcohol use T3b
Alcohol-specific rules (time-varying)Child disclosure (time-invariant)
Class composition (time-invariant)
Fig. 1 Moderation model of the association between age at menarche, alcohol-specific rules, child disclosure, class gender composition and
adolescent girls’ alcohol use. a Only for non-drinking girls. b Only for drinking girls
J Youth Adolescence
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alcohol, increasing to 62.3 % at T3. Average weekly alcohol
use reported by the drinking adolescent girls also increased
from T0 to T3, from 2.45 to 7.04 glasses per week. However,
even though the percentage of drinkers increased from T1 to
T2, from 28.8 to 44.9 %, the average weekly alcohol use of
the drinking adolescent girls remained stable between these
two waves. Alcohol-specific rules decreased over time,
indicating that parents became less restrictive regarding
adolescent alcohol use. In addition, the standard deviation of
alcohol-specific rules increased over the different waves,
showing more variation in parental rules over time. Con-
cerning the intercorrelations, younger age at menarche was
related to less alcohol use only at T1 (r = -.24, p = .035).
Furthermore, alcohol-specific rules were related negatively
to alcohol use at all waves (r = -.22 to -.62).
Predicting Onset of Adolescent Alcohol Use
In Table 2, the main effects of the predictor variable, age at
menarche, and the moderator effects of alcohol-specific
rules, child disclosure and class gender composition are
presented separately for alcohol onset at T1, T2 and T3.
Interactions between age at menarche and the moderating
variables were examined and insignificant interactions
were deleted from the model; significant interactions with
age at menarche are presented in Table 2.
Onset of alcohol use at T1 was increased significantly by
age at menarche (B = -0.45, SE B = 0.17, OR = 0.64,
p = .048), indicating that early-maturing girls had a higher
probability to drink alcohol at T1. Furthermore, onset of
alcohol use at T1 was associated negatively with alcohol-
specific rules at T0 (B = -0.92, SE B = 0.33, OR = 0.40,
p = .006) and with child disclosure (B = -1.39, SE
B = 0.28, OR = 0.25, p \ .001). In addition to these main
effects, a significant interaction effect was found between
age at menarche and class gender composition (B =
-2.73, SE B = 1.38, OR = 0.06, p = .048). Additional
analyses showed that the effect of age at menarche was
only significant for adolescent girls in classes with a
moderate to high percentage of girls (scores [ 0.47,
n = 188). This interaction effect is plotted in Fig. 2. Sep-
arate lines refer to the effect of age at menarche on onset of
alcohol use, for different values of class gender composi-
tion. To determine these values, we used the results of the
MODPROBE approach, namely the lowest value of class
gender composition (0.47) where the effect of age at
menarche on onset of alcohol use is significant, the mean
value (0.58) and the highest value (0.75). This figure shows
that the interaction between age at menarche and class
gender composition is most relevant for predicting onset of
alcohol use in early adolescence, when girls are 13 years or
younger.
Concerning T2, onset of alcohol use was increased
significantly by age at menarche again (B = -0.33, SE
B = 0.15, OR = 0.72, p = .041). Onset of alcohol use at
T2 was related negatively to child disclosure as well
(B = -0.67, SE B = 0.26, OR = 0.51, p = .011). In
addition, one interaction effect proved to be significant,
namely between age at menarche and alcohol-specific rules
at T1 (B = -0.67, SE B = 0.30, OR = 0.51, p = .024).
Additional analyses showed that the effect of age at men-
arche was only significant for adolescent girls with
restrictive parents (scores [ 4.43, n = 212), and not for
adolescent with lenient parents. In Fig. 3 this interaction
effect is presented, with separate lines for the lowest value
of alcohol-specific rules (4.43) where the effect of age at
Table 1 Intercorrelations and descriptive statistics of model variables (N = 430)
Variable 1 2 3 4 5 6 7 8 9 10 11
1. Age at menarche (in years) –
2. Alcohol use T0a (n = 96, 22.3 %) -.12 –
3. Alcohol use T1a (n = 128, 28.8 %) -.24* .44** –
4. Alcohol use T2a (n = 193, 44.9 %) -.16 .21** .54** –
5. Alcohol use T3a (n = 268, 62.3 %) -.03 .23** .55** .58** –
6. Alcohol-specific rules T0 .11* -.61** -.48** -.19* -.22** –
7. Alcohol-specific rules T1 .15** -.20 -.49** -.32** -.26** .56** –
8. Alcohol-specific rules T2 .09 -.26* -.35** -.41** -.28** .48** .65** –
9. Alcohol-specific rules T3 .05 -.16 -.35** -.35** -.35** .42** .55** .68** –
10. Child disclosure T0–T3 .12* -.26* -.22* -.22* -.27** .20** .30** .31** .25** –
11. Class gender composition T0 .03 -.04 -.06 .06 .17** -.03 .06 .01 .03 .01 –
M 12.73 2.45 5.76 5.70 7.04 4.53 4.36 4.10 3.84 4.02 0.50
SD 0.96 2.67 8.09 7.95 8.23 0.56 0.68 0.76 0.95 0.58 0.12
Skewness 0.05 1.37 1.23 1.17 1.08 -1.04 -1.01 -0.95 -0.62 -0.64 0.33
a Calculated using only the drinking adolescent girls at each wave
* p \ .05, ** p \ .01
J Youth Adolescence
123
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spec
ific
rule
sT
0-
0.9
2(0
.33
)**
0.4
0[0
.21
,0
.77
]0
.04
(0.3
6)
1.0
4[0
.51
,2
.11
]-
0.6
1(0
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)0
.54
[0.2
6,
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4]
Alc
oh
ol-
spec
ific
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sT
1-
0.2
8(0
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.76
[0.4
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-0
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0.9
3[0
.46
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.90
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Alc
oh
ol-
spec
ific
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[0.2
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Ch
ild
dis
clo
sure
T0
–T
3-
1.3
9(0
.28
)**
*0
.25
[0.1
4,
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-0
.67
(0.2
6)*
0.5
1[0
.30
,0
.86
]-
0.1
9(0
.29
)0
.83
[0.4
7,
1.4
6]
Cla
ssg
end
erco
mp
osi
tio
nT
00
.76
(1.2
7)
2.1
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[0.1
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9.7
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.62
(1.2
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0[0
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]
Ste
p3
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eat
men
arch
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]
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spec
ific
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sT
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eat
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1
J Youth Adolescence
123
Page 8
menarche on onset of alcohol use is significant, the mean
value (4.83) and the highest value (5.00). This figure shows
that the effect of the interaction between age at menarche
and alcohol-specific rules at T1 changes during adoles-
cence. Strict alcohol-specific rules are related to a higher
probability of onset of alcohol use in early adolescence, but
the opposite seems to be the case in later stages of ado-
lescence. Yet, the differences between the different values
of alcohol-specific rules are quite small.
In contrast with onset of alcohol use at T1 and T2, onset at
T3 was not related significantly to age at menarche. Results
showed that onset of alcohol use at T3 was only related
negatively to alcohol-specific rules at T2 (B = -0.81, SE
B = 0.29, OR = 0.45, p = .005). No further significant
effects were found for onset of alcohol use at T3.
Taken together, results show that the probability of
onset of adolescent alcohol use was increased significantly
by younger age at menarche, but only for onset at T1 and
T2. In addition, alcohol-specific rules were related nega-
tively to onset at T1 and T3, child disclosure to onset at T1
and T2. Moderation analyses showed that a higher risk of
onset of alcohol use in early-maturing girls existed only for
girls with high levels of alcohol-specific rules and for girls
in classes with a moderate to high percentage of girls.
Predicting the Level of Adolescent Alcohol Use
In Table 3, main effects and significant interaction effects
are presented for the variables predicting the level of ado-
lescent alcohol use in girls that are already drinking, sepa-
rately for the level of alcohol use at T1, T2 and T3. In these
analyses, we controlled for previous alcohol consumption.
The level of alcohol use at T1 was associated negatively with
alcohol-specific rules at T0 (B = -2.90, SE B = 1.32,
p = .030, b = -.24) and with previous alcohol use. No
further effects were found for level of alcohol use at T1.
The level of alcohol use at T2 was associated positively
only with previous alcohol use. No significant effects were
found for either age at menarche or the moderator
variables.
The level of adolescent alcohol use at T3 was associated
positively with class gender composition (B = 12.53, SE
B = 3.36, p \ .001, b = .19), with a higher percentage of
girls in classes being related to higher alcohol use. Previous
Fig. 3 Visualization of the
effect of the interaction between
age at menarche and alcohol-
specific rules at T1 on onset of
alcohol use at T2, presented for
different values of the
moderating variable
Fig. 2 Visualization of the
effect of the interaction between
age at menarche and class
gender composition on onset of
alcohol use at T1, presented for
different values of the
moderating variable
J Youth Adolescence
123
Page 9
alcohol use was also a significant predictor. Next to these
main effects, the interaction between age at menarche and
class gender composition proved to be significant
(B = 10.57, SE B = 3.71, p = .005, b = .14). Additional
analyses showed that the effect of age at menarche was only
significant for adolescent girls in classes with a moderate to
high percentage of girls (scores [ 0.41, n = 136). In Fig. 4
this interaction effect is presented, with separate lines for the
lowest value of class gender composition (0.41) where the
effect of age at menarche on onset of alcohol use is signifi-
cant, the mean value (0.57) and the highest value (0.75). This
figure shows that the interaction between age at menarche
and class gender composition is particularly of importance in
later stages of adolescence, as the differences between the
separate lines increase with age.
Taken together, the results indicate that younger age at
menarche is not a significant predictor of the level of
alcohol use. Previous alcohol use, however, is related
positively to level of alcohol use. For predicting the level
of alcohol use at T1, a negative association was present
with alcohol-specific rules at T0. Child’s disclosure proved
to be a significant predictor for level of alcohol use at T2,
Table 3 Results of hierarchical linear regression analyses of age at menarche, alcohol-specific rules, behavioral problems, child disclosure and
class gender composition on the level of adolescent alcohol use
Predictor Level alcohol use T1
(n = 96)aLevel alcohol use T2
(n = 128)bLevel alcohol use T3
(n = 193)c
B (SE) b B (SE) b B (SE) b
Step 1
Age at menarche -1.38 (0.69) -.18 -0.37 (0.59) -.05 0.94 (0.47) .02
Level of alcohol use T0 1.46 (0.26)*** .50 0.79 (0.27)** .25 -0.26 (0.38) -.05
Level of alcohol use T1 0.70 (0.09)*** .67 0.46 (0.11)*** .32
Level of alcohol use T2 0.70 (0.08)*** .55
Step 2
Alcohol-specific rules T0 -2.90 (1.32)* -.24 0.10 (1.18) .01 -0.92 (1.05) -.06
Alcohol-specific rules T1 -0.89 (0.91) -.09 -0.01 (0.87) -.00
Alcohol-specific rules T2 0.63 (0.73) .06
Child disclosure T0–T3 -1.45 (0.91) -.14 -1.58 (0.79)* -.15 -0.28 (0.70) -.02
Class gender composition T0 -0.06 (5.17) -0.00 5.46 (4.06) 0.10 12.53 (3.36)*** .19
Step 3
Age at menarche * Class gender composition 10.57 (3.71)** .14
a Step 1 (including age at menarche and prior level alcohol use): adjusted R2 = .28. Step 2 (1 ? main effects): D adjusted R2 = .04, p = .049b Step 1: adjusted R2 = .33. Step 2 (1 ? main effects): D adjusted R2 = .01, p = .192c Step 1: adjusted R2 = .52. Step 2: D adjusted R2 = .04, p = .011. Step 3 (2 ? interaction effects): D adjusted R2 = .02, p = .005
* p \ .05, ** p \ .01
Fig. 4 Visualization of the
effect of the interaction between
age at menarche and class
gender composition on level of
alcohol use at T3, presented for
different values of the
moderating variable
J Youth Adolescence
123
Page 10
class gender composition for level of alcohol use at T3.
Moderation analyses showed that the effect of age at
menarche on level of alcohol use at T3 existed only for
girls in classes with a moderate to high level of girls.
Discussion
Younger age at menarche is associated with a higher risk of
involvement in deviant behaviors, such as alcohol use (e.g.,
Deardorff et al. 2005). However, previous studies rarely
differentiated between the onset and level of drinking, or
investigated the relationship between age at menarche and
alcohol use across different subgroups. The focus of this
study was to examine the relationship between age at
menarche and alcohol use among adolescent girls, while
distinguishing between the onset and subsequent level of
alcohol use. Findings show that, as hypothesized, younger
age at menarche (i.e., earlier pubertal timing) is a risk factor
for the onset of adolescent alcohol use, but not for the
subsequent progress in consumption of alcohol use. Results
further show that younger age at menarche increased the risk
of onset of alcohol use only at T1 and T2, when girls were
aged 13 and 14, indicating that early-maturing girls initiate
alcohol use at a younger age than other girls. However, age
at menarche is not related to onset of alcohol use at T3,
which indicates that the risk factor early pubertal timing is
only manifest at the early stages of adolescence. This is
consistent with previous research (e.g., Kaltiala-Heino et al.
2011). Later in adolescence, when more girls have reached
puberty, the differences between earlier- and later-maturing
girls may disappear when most girls started to mature. At
this point, early-maturing girls are not treated differently by
others anymore, which is in accordance with the early-tim-
ing hypothesis. This might clarify the disappearance of the
effect of age at menarche later in adolescence. Furthermore,
girls were on average 15.32 years old at T3. At this age,
adolescents are reaching late adolescence, a period in which
normative rates of adolescent drinking accelerate quickly
(Chartier et al. 2010). Studies have shown that adolescent
alcohol use is relatively common in this age period (e.g.,
Johnston et al. 2009), in particular in the Netherlands (Si-
mons-Morton et al. 2010). Thus, the fact that alcohol use
becomes more common later in adolescence might also
explain the disappearance of the effect of age at menarche.
As the negative effects of pubertal timing might differ
between individuals, we examined alcohol-specific rules,
children’s disclosure and class gender composition as
additional risk factors. Contrary to our expectations, the
negative effect of age at menarche on onset of alcohol use
exists mainly for girls with a high level of alcohol-specific
parental rules. Apparently, in the presence of additional
risk factors, younger age at menarche does not have any
additional explanatory power. Multiple studies have indeed
demonstrated the strong effects of other risk factors on the
onset of adolescent alcohol use, such as parenting behavior
(Ge et al. 2002; Westling et al. 2008) or adverse childhood
experiences (Rothman et al. 2008). However, future
research is needed to replicate this finding. The fact that
younger age at menarche stands out as a risk factor only in
adolescent girls with a low level of additional risk factors
could be explained by the social push hypothesis, stating
that when children lack social factors that ‘‘push’’ to
problem behavior, biological factors are more likely to
explain this behavior. So, due to the low level of social risk
factors in these girls, younger age at menarche becomes an
important predictor. Another possibility is that there is a
limit to how strict parents can be concerning adolescents’
alcohol use. Previous research showed that authoritarian
parents were less successful in reducing adolescents’
alcohol use than authoritative parents (Adalbjarnardottir
and Hafsteinsson 2001). In the case of too strict alcohol-
specific rules, early-maturing girls could start to oppose
their parents by starting to drink alcohol. However, more
research is needed to examine whether these arguments
could explain the effects found in low risk girls.
Looking at the other outcome examined in the present
study, the level of alcohol use of girls that have started
drinking, results showed that the previous level of alcohol
use was the most important predictor. Only three other
main effects were found, namely of alcohol-specific rules
(T1), children’s disclosure (T2), and class gender compo-
sition (T3), with a lower level of parental rules, a lower
level of children’s disclosure, and a higher percentage of
girls being related to more alcohol use. Apparently, risk
factors have more explanatory power for the onset of
alcohol than for the subsequent alcohol consumption,
which is in line with our hypotheses. One possible expla-
nation could be that, once adolescent girls started drinking
alcohol, and discovered the effects of it, subsequent alcohol
use is internally motivated. For example, girls could con-
tinue their alcohol use because they enjoy the relaxing
effect. Studies have indeed found that adolescents use
alcohol to deal with the stress in their lives (e.g., Bray et al.
2001). However, as no measures concerning stress were
included in this study, future research is needed to examine
this potential explanation.
Lastly, class gender composition appeared to be of
interest. The results show that younger age at menarche
was related to higher levels of alcohol use only for
adolescent girls in classes with a moderate to high per-
centage of girls. This result, however, is not in line with
previous literature, which stated that early-maturing girls
were more at risk when they were surrounded by many
boys. It might be that adolescent girls feel safer to drink
with same-sex peers, which might increase the level of
J Youth Adolescence
123
Page 11
alcohol they consume. Such reasoning was provided by
girls using marijuana in the study of Haines et al. (2009).
It was stated that, in a mixed-sex setting, girls have to be
careful, as boys want to get girls high for sex. This may
also apply to alcohol use: in all-girl settings, such caution
is not necessary and girls feel more secure and thus drink
more alcohol. This might explain why the risk of a higher
level of alcohol use exists only for early-maturing girls in
classes with a moderate to high percentage of girls. These
findings (especially for predicting alcohol use at T3) may
be related to the Dutch school system. This is because
from the first year of secondary school, when most pupils
are 12–13 years of age, the Dutch educational system is
already highly differentiated. Depending on their teacher’s
advice and the results of a test in the last year of primary
education, pupils enter different types of secondary edu-
cation. The educational levels are: pre-vocational educa-
tion, lower general secondary education, upper-general
secondary education and pre-university education. Most
adolescents remain in the same level of education
throughout high school. In addition, classes in Dutch
secondary schools are strongly organized by classrooms,
indicating that students spend most of their school time
with the same peers who have a similar educational level.
As contact with students from other classes is limited, this
might explain the long-lasting effect of class gender
composition. Yet, little is known about the effect of class
gender composition, more research is needed to replicate
these findings and provide additional explanations.
Limitations
This study has several limitations. The results of are based
upon adolescent self-report data. Even though the use of
multiple informants is preferred, self-report measures have
proven to be reliable concerning alcohol use (Koning et al.
2010b) and age at menarche (Smolak et al. 2007) and are
often used in previous studies. Secondly, more detailed
information about peer influences is preferred. This is
because class gender composition was hypothesized to
influence the relationship between age at menarche and
alcohol use, due to the influence of male peers. However,
we were unable to test this hypothesis directly, as no direct
information was available about interactions with peers.
Ideally, one would like to know the proportion of male
peers of the adolescent girls, including information about
their drinking behavior. Furthermore, as peer relationships
can also be formed outside the school environment, more
specific peer related factors should be included in future
research, making it possible to examine the influence of
male peers more directly. Lastly, even though we tried to
incorporate the higher level structure of classes by exam-
ining the effect of class gender composition, future
research might benefit from examining this multilevel
structure more clearly by using multilevel methods.
Implications
The results of this study have various implications. First,
more insight has been provided concerning the relationship
between age at menarche and alcohol use, showing that it is
important to distinguish between onset and subsequent
level of alcohol use. Results indicate that age at menarche
only influences onset during early and middle adolescence;
not during late adolescence when alcohol use becomes
normative. So, when wanting to prevent the initiation of
alcohol use, it is important to look at the age of adolescent
girls. Furthermore, although this study is not the first to
distinguish between the onset and level of alcohol use (e.g.,
Costello et al. 2007; Lanza and Collins 2002), it appears to
be the first to look at the moderating role of several risk
factors. Results indicate that younger age at menarche
increases the risk of onset of alcohol use only in adolescent
girls with a low level of additional risk factors. In addition,
the negative effect of age at menarche on subsequent
drinking behavior is present only in adolescent girls in
classes with a moderate to high percentage of girls. This
indicates that interventions targeting adolescent alcohol use
need to pay attention to these additional risk factors. Lastly,
we showed that the effect of age at menarche on onset of
alcohol use exists only for those adolescent girls reporting
restrictive alcohol-specific rules. Parents should be made
aware of the possible negative side-effects of too strict
rules, hereby reducing the risk of onset of alcohol use for
early-maturing girls.
Conclusions
The current study adds to previous research by distin-
guishing between the onset and subsequent level of ado-
lescent alcohol use, in examining the effect of age at
menarche. In addition, several contextual moderators were
examined. Results indicated that younger age at menarche
was related to the onset of alcohol use only in early and
middle adolescence. This effect was only present in low
risk girls, with high levels of alcohol-specific rules and in
classes with a moderate to high percentage of girls. These
results hold valuable information for interventions aiming
to decrease adolescent alcohol use. For example, taking
into account the role of alcohol-specific rules, the aware-
ness of being too strict as a parent should be increased. In
addition, our results indicate that keeping adolescent girls
away from older boys might also not be the most effective
strategy, as effects were strongest in classes with a mod-
erate to high percentage of girls. In conclusion, our results
J Youth Adolescence
123
Page 12
show that it is necessary to also focus on low risk ado-
lescent girls, as low risk girls, particularly those with a
younger age at menarche, can also become involved in
problematic behavior during adolescence.
Author contributions MV coordinated and drafted the manuscript,
performed the statistical analyses and the interpretation of the data.
RJJME participated in the design of the study and helped with the
interpretation of the data and the draft of the manuscript. IMK
coordinated the study, performed the measurements and helped to
draft the manuscript. WAMV participated in the design and the
coordination of the study and helped to interpret the data and draft the
manuscript. All authors read and approved the final manuscript.
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Author Biographies
Melissa Verhoef is a Ph.D. candidate at the Faculty of Social and
Behavioral Sciences at Utrecht University. Her research interests
include child and adolescent well-being and family relationships.
Regina J. J. M. van den Eijnden is an Assistant Professor at the
Faculty of Social and Behavioral Sciences at Utrecht University. She
received her Ph.D. at the University of Groningen in 1998. Her main
research interests are adolescents’ and young adults’ addiction
behaviours.
Ina M. Koning is a Postdoctoral Researcher at the Faculty of Social
and Behavioral Sciences at Utrecht University where she also
obtained her Ph.D. in 2011. Her research interests include the
prevention of alcohol use in adolescents and the influence of parents
on adolescents’ drinking behavior.
Wilma A. M. Vollebergh is a Professor at the Faculty of Social and
Behavioral Sciences of Utrecht University. She received her Ph.D. at
Utrecht University in 1991. She is the director of research and
program coordinator of ‘‘Youth in Changing Cultural Contexts’’. Her
research focuses on developmental trajectories of mental health and
substance (ab)use in adolescence and early adulthood.
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