Home | About | Journals | Submit | Contact Us | Français |

**|**Elsevier Sponsored Documents**|**PMC2877869

Formats

Article sections

Authors

Related links

Ann Epidemiol. 2010 May; 20(5): 405–408.

PMCID: PMC2877869

Krista Yorita Christensen,^{a,}^{} Mildred Maisonet,^{a,}^{b} Carol Rubin,^{b} W. Dana Flanders,^{a,}^{b} Carolyn Drews-Botsch,^{a} Celia Dominguez,^{c} Michael A. McGeehin,^{b} and Michele Marcus^{a,}^{b}

Krista Yorita Christensen: moc.liamg@atiroylk

Received 2009 November 5; Accepted 2010 February 5.

Copyright © 2010 Elsevier Inc.

This document may be redistributed and reused, subject to certain conditions.

This document was posted here by permission of the publisher.
At the time of the deposit, it included all changes made during peer review,
copy editing, and publishing. The U. S. National Library of Medicine is responsible
for all links within the document and for incorporating any publisher-supplied
amendments or retractions issued subsequently. The published journal article,
guaranteed
to be such by Elsevier, is available for free, on ScienceDirect, at: http://dx.doi.org/10.1016/j.annepidem.2010.02.005

This article has been cited by other articles in PMC.

The timing of breast and pubic hair development in girls are related, but the degree of correlation has not been well characterized. Periodic observations also are complicated by interval censoring.

Data used were from the Avon Longitudinal Study of Parents and Children. Mean age at entry into breast and pubic hair development was determined by the use of parametric survival analysis. The bivariate normal cumulative distribution function was evaluated over the region containing the paired event times; the likelihood was maximized with respect to the correlation coefficient ρ.

Among 3938 participants, estimated mean ages at entry into Tanner stage 2 for breast and pubic hair development were 10.19 and 10.95, respectively. The likelihood was maximized at ρ = 0.503 to 0.506. This value remained relatively constant among subgroups, although some heterogeneity was observed by maternal and child body mass index and birth order.

The timing of breast and of pubic hair development is moderately correlated and remain so when it is stratified by characteristics associated with puberty.

Although average ages at attainment of female secondary sexual characteristics have been estimated for various populations, the interrelationship of the timing of these events is not well characterized. One reason is that many studies of puberty are cross-sectional in nature, using “status quo” assessments of development, to generate population estimates of timing of various stages. However, individual-level estimates are not possible in a cross-sectional setting. Consequently, if individuals are not followed over time, it is difficult to estimate the correlation between the ages at beginning breast development and pubic hair development because both of these events are not likely to be observed in the same girl. Even in longitudinal studies, the exact timing of events may not be known because the transition generally occurs between study assessments or clinic visits. This phenomenon of interval censored data, where the event is only known to occur within some interval, must be accounted for in estimating age at event.

In the few longitudinal studies that have attempted to estimate the correlation between beginning breast and pubic hair development, two approaches have been used. These are (i) estimate age at event as the age at the first “post-event” study assessment, or (ii) estimate age at event as the midpoint between the last “pre-event” assessment and the first “post-event” assessment. The first method is likely to skew the age distribution toward older ages; the second method is more likely to estimate age at event correctly but also could present problems if there are few assessments or long intervals between assessments.

These methodological considerations may explain some of the variation in estimated correlation between age at beginning breast and pubic hair development among studies. Largo et al. (1) estimated a correlation of 0.34 among girls participating in the First Zurich Longitudinal study, while Nicholson et al. (2) report a correlation of 0.74 among girls participating in the Guidance Study (Table 1) (1–4). Estimates from the Swedish Growth study (3) and the Fels study (4) are intermediate (0.70 and 0.66, respectively). Notably, these studies were reported between 1948 and 1983; there are no estimates from a contemporary longitudinal cohort. Further, it is not known which demographic or physiological characteristics might have an impact on the relationship between timing of breast and pubic hair development.

We used the Avon Longitudinal Study of Parents and Children (ALSPAC) to estimate the correlation between ages at beginning breast and pubic hair development by using a maximum likelihood approach adapted to accommodate interval censored data.

When considering breast and pubic hair development separately, age at occurrence may be treated as a survival time, perhaps following a univariate normal distribution. To characterize the relationship between ages at the two events, a natural extension is the bivariate normal distribution. Parametric survival analyses allow the estimation of the mean (and standard deviation) age at event. However, the correlation between ages at occurrence of the two events is not easily obtained. Most extensions of survival analysis for multiple outcomes use stratification or competing risk scenarios, in which the correlation is either accounted for but not estimated or only one outcome is observed per individual. A further difficulty is introduced by interval censoring of event times. To estimate the correlation between ages at occurrence of two distinct and observed events, a maximum likelihood approach will be used, with modification to accommodate the interval censored nature of the available data.

A pair of event times, defined as *X* for the first event and *Y* for the second, follow some joint probability density distribution *f _{X,Y}*(

$$f\left(x,y\right)=\frac{1}{2\pi {\sigma}_{x}{\sigma}_{y}\sqrt{\left(1-{\rho}^{2}\right)}}\mathrm{exp}\left[\frac{-1}{2\left(1-{\rho}^{2}\right)}\left[{\left(\frac{x-{\mu}_{x}}{{\sigma}_{x}}\right)}^{2}+{\left(\frac{y-{\mu}_{y}}{{\sigma}_{y}}\right)}^{2}-2\rho \left(\frac{x-{\mu}_{x}}{{\sigma}_{x}}\right)\left(\frac{y-{\mu}_{y}}{{\sigma}_{y}}\right)\right]\right]$$

(1)

whereas *F*(*x*, *y*) takes the following form (equation 2):

$${F}_{X,Y}\left(x,y\right)=\underset{-\mathrm{\infty}}{\overset{x}{\int}}\underset{-\mathrm{\infty}}{\overset{y}{\int}}f\left(x,t\right)dsdt$$

(2)

Because there is no closed expression for *F _{X,Y}*(

In the case of interval censoring, *X* and *Y* are not observed directly, but are known to fall within a certain interval; in the case of left and right censoring, the end point of the interval is negative or positive infinity, respectively. These intervals are indicated as (L_{x}, R_{x}) for the interval containing x, and (*L _{y}*,

This method was used to estimate the correlation between age at entry into Tanner stage 2 (or greater, if stage 2 is not observed) of breast and of pubic hair development among girls participating in the ALSPAC (8). The physical development of this cohort has been assessed by the use of annual questionnaires that ascertain Tanner stage of breast and pubic hair development (self-assessed at time of questionnaire completion), mailed to participants from the ages of 8 to 14. Because data were collected annually, entry into breast and pubic hair development is known to occur within intervals defined by timing of questionnaire completion. The median age at entry for each marker and accompanying standard deviation were calculated by the use of the LIFEREG procedure in SAS (SAS Institute, Cary, NC), with interval censoring and the normal distribution specified. This median age is equivalent to the mean, attributable to the normal distribution assumption and the fact that the event occurs within a very specific timeframe during which there are no outliers or skewness. Then, the likelihood procedure was implemented in SAS by use of the PROBBNRM function to estimate the cumulative distribution function of the bivariate normal distribution.

To determine whether the correlation between ages at entry into breast and pubic hair development is a function of some underlying variable, the analysis was repeated for selected maternal and child characteristics that are not intermediate between breast and pubic hair development and are known to be associated with pubertal development. These included mother's prepregnancy body mass index (BMI), birth order, child's BMI at age 8, and child's race. Human subject protection was assessed and approved by the ALSPAC Law and Ethics Committee, the Local Research Ethics Committees, and the Centers for Disease Control and Prevention Institutional Review Board.

There were 3938 participants with information on breast and pubic hair development. Among these girls, the mean ages at entry into breast stage 2 and pubic hair stage 2 were estimated to be 10.19 (SD 1.52) and 10.95 (SD 1.42). There were 1000 girls who were left censored for age at entry into breast stage 2, and 608 who were left censored for age at entry into pubic hair stage 2; 469 and 712 girls were right censored for age at entry into breast and pubic hair stage 2, respectively. For these girls, the left interval end point was set at (μ – 4*σ) and the right interval endpoint at (μ + 4*σ) as appropriate, where μ and σ represent the estimated mean and standard deviation of age at entry, respectively. The likelihood was evaluated over the range of the correlation coefficient ρ, from −0.999 to 0.999. The negative of the natural log of the likelihood was minimized when ρ reached a value of 0.50.

The correlation between ages at entry into breast and pubic hair stage 2 was similar between subgroups on the basis of maternal and child characteristics associated with pubertal development (Table 2). The greatest difference was found by BMI. The correlation was greatest among girls who were underweight (0.59) or whose mothers were underweight (0.57) and lowest among girls who were overweight or obese (0.31–0.41) or whose mothers were classified as obese (0.41). Correlations ranged from 0.46 to 0.57 when birth order was examined and from 0.50 to 0.53 depending on child's race.

To evaluate the performance of the maximum likelihood approach, the correlation was also estimated by the use of either the end of the interval (i.e., age at completing questionnaire where event is first recorded) or the midpoint of the interval (i.e., age intermediate between questionnaires immediately preceding the event and where event is first recorded). These approaches did not substantially change the estimate of ρ (ρ = 0.56 and 0.50, respectively).

We used data from a contemporary, representative cohort of girls to estimate the correlation between ages at entry into stage 2 of breast and of pubic hair development. By using a novel application of a likelihood maximization technique, we found that approximately one half of the variation in timing of breast development is explained by the variation in timing of pubic hair development, an estimate that is intermediate between (and somewhat lower than most of) previously reported correlations. Reasons for the difference between the present and previously reported studies include use of a different estimation method, different populations and timing, and differences in frequency of study assessments.

It is expected that the timing of breast and pubic hair development will be related because the cascade of events for both is ultimately regulated by the central nervous system. However, the moderate degree of association estimated in this study is consistent with the biology of breast and pubic hair development, which are governed by the hypothalamic pituitary gonadal axis and hypothalamic pituitary adrenal axis, respectively, and thus may not be expected to display a high degree of dependence. Environmental exposures or genetic characteristics that alter production of or response to androgens would be expected to impact timing of pubic hair development, whereas those factors affecting estrogen would have an impact on the timing of breast development. In either case, such disruption could lower the correlation between ages at entry into these developmental milestones.

The magnitude of the association between timing of the two markers was similar within strata of characteristics associated with pubertal development, suggesting that timing of breast and pubic hair development are not independent. That is, differences in the relative timing of breast and pubic hair development do not appear to be caused by the demographic characteristics explored in this analysis. There was some heterogeneity by both child and maternal BMI, however, and the correlation was greatest among underweight girls and girls whose mothers were underweight and lowest among heavier girls and girls whose mothers were heavier. The similarity in pattern by child and maternal BMI may be attributable to the fact that maternal BMI acts as a proxy for girl's BMI (9, 10). Girls who are more overweight may mistake adipose tissue for more advanced breast development, creating spurious differences in timing of maturation for breast and pubic hair development (11, 12).

There were some limitations to these analyses. The correlation represents a linear relationship between variables and thus does not capture more complex dependence that may exist between timing of breast and pubic hair development. Entry into stage 2 was not observed for some girls, only transition from stage 1 to stage ≥3. Because data were collected on an annual basis, events occurring months apart are likely to be reported in the same questionnaire year, which could artificially inflate our estimate of correlation between event times. Finally, correlation is influenced by variance of the individual random variables and covariance between them (13), which may affect subgroup analyses. However, the decreased correlation with greater BMI shows a dose-response relationship not explained by within-strata variance alone.

We considered various distributions in the univariate survival analysis. Mean and median time at entry into breast and pubic hair development were similar under varying distributional assumptions, so the normal distribution was chosen for ease of interpretation. However, this method could be extended to other bivariate distributions, and to higher order distributions, maximizing the likelihood with respect to the covariance matrix. This application of maximum likelihood analysis to interval censored puberty data provides a novel approach for assessing the relationship between timing of milestones in growth and development.

We are extremely grateful to all the families who took part in this study, the midwives for their help in recruiting them, and the entire ALSPAC team, including interviewers, computer and laboratory technicians, clerical workers, research scientists, volunteers, managers, receptionists and nurses.

This work was supported by the Centers for Disease Control and Prevention. The UK Medical Research Council; the Wellcome Trust; and the University of Bristol provide core support for ALSPAC.

1. Largo R.H., Prader A. Pubertal development in Swiss girls. Helv Paediatr Acta. 1983;38(3):229–243. [PubMed]

2. Nicolson A.B., Hanley C. Indices of physiological maturity: Derivation and interrelationships. Child Dev. 1953;24(1):3–38. [PubMed]

3. Taranger J., Engstrom I., Lichtenstein H., Svennberg-Redegren I.V.I. Somatic pubertal development. Acta Paediatr Scand Suppl. 1976;1976(258):121–135. [PubMed]

4. Reynolds E.L., Wines J.V. Individual differences in physical changes associated with adolescence in girls. Am J Dis Child. 1948;75(3):329–350. [PubMed]

5. Betensky R.A., Finkelstein D.M. A non-parametric maximum likelihood estimator for bivariate interval censored data. Stat Med. 1999;18(22):3089–3100. [PubMed]

6. Peto R. Experimental survival curves for interval-censored data. J Roy Stat Soc Ser C. 1973;22(1):86–91.

7. Turnbull B.W. Empirical distribution function with arbitrarily grouped, censored and truncated data. J Roy Statl Soc Ser B. 1976;38(3):290–295.

8. Golding J., Pembrey M., Jones R. ALSPAC—the Avon Longitudinal Study of Parents and Children. I. Study methodology. Paediatr Perinat Epidemiol. 2001;15(1):74–87. [PubMed]

9. Lake J.K., Power C., Cole T.J. Child to adult body mass index in the 1958 British birth cohort: Associations with parental obesity. Arch Dis Child. 1997;77(5):376–381. [PubMed]

10. Whitaker R.C., Wright J.A., Pepe M.S., Seidel K.D., Dietz W.H. Predicting obesity in young adulthood from childhood and parental obesity. N Engl J Med. 1997;337(13):869–873. [PubMed]

11. Biro F.M., Lucky A.W., Simbartl L.A., Barton B.A., Daniels S.R., Striegel-Moore R. Pubertal maturation in girls and the relationship to anthropometric changes: Pathways through puberty. J Pediatr. 2003;142(6):643–646. [PubMed]

12. Wang Y. Is obesity associated with early sexual maturation? A comparison of the association in American boys versus girls. Pediatrics. 2002;110(5):903–910. [PubMed]

13. Kleinbaum D.G., Kupper L.L., Miller K.E., Nizam A. 3rd ed. Brooks/Cole Publishing Company; Pacific Grove, CA: 1998. Applied Regression Analysis.

PubMed Central Canada is a service of the Canadian Institutes of Health Research (CIHR) working in partnership with the National Research Council's national science library in cooperation with the National Center for Biotechnology Information at the U.S. National Library of Medicine(NCBI/NLM). It includes content provided to the PubMed Central International archive by participating publishers. |