- Research article
- Open Access
Early-life exposures and age at thelarche in the Sister Study cohort
Breast Cancer Research volume 23, Article number: 111 (2021)
Early age at breast development (thelarche) has been associated with increased breast cancer risk. Average age at thelarche has declined over time, but there are few established risk factors for early thelarche. We examined associations between pre- and postnatal exposures and age at thelarche in a US cohort of women born between 1928 and 1974.
Breast cancer-free women ages 35–74 years who had a sister diagnosed with breast cancer were enrolled in the Sister Study from 2003 to 2009 (N = 50,884). At enrollment, participants reported information on early-life exposures and age at thelarche, which we categorized as early (≤ 10 years), average (11–13 years), and late (≥ 14 years). For each exposure, we estimated odds ratios (ORs) and 95% confidence intervals (CIs) for early and late thelarche using polytomous logistic regression, adjusted for birth cohort, race/ethnicity and family income level in childhood.
Early thelarche was associated with multiple prenatal exposures: gestational hypertensive disorder (OR = 1.25, 95% CI 1.09–1.43), diethylstilbestrol use (OR = 1.23, 95% CI 1.04–1.45), smoking during pregnancy (OR = 1.20, 95% CI 1.13–1.27), young maternal age (OR 1.30, 95% CI 1.16–1.47 for < 20 vs. 25–29 years), and being firstborn (OR = 1.25, 95% CI 1.17–1.33). Birthweight < 2500 g and soy formula use in infancy were positively associated with both early and late thelarche.
Associations between pre- and postnatal exposures and age at thelarche suggest that the early-life environment influences breast development and therefore may also affect breast cancer risk by altering the timing of pubertal breast development.
While age at menarche is an established breast cancer risk factor , earlier age at onset of breast development (thelarche) has also recently been linked to increased breast cancer risk, independent of age at menarche [2, 3]. Identifying modifiable risk factors associated with early thelarche may provide an opportunity for primary prevention of breast cancer by delaying the onset of pubertal breast development. Apart from larger childhood body size [4, 5], however, there are few established risk factors for early thelarche.
A recent meta-analysis estimated that age at thelarche has declined at a rate of 3-months per decade over the past 50 years . This rapid rate of decline suggests that environmental factors, acting independently or interacting with genetic susceptibility, are driving the secular trend . Factors hypothesized to influence the timing of thelarche include nutritional factors, psychosocial stressors, and exposure to endocrine-disrupting chemicals, as well as conditions affecting the intrauterine environment [6,7,8].
Our objective was to examine associations between pre- and postnatal exposures and age at thelarche in a prospective US cohort of women born between 1928 and 1974. We further examined whether associations between early-life exposures and age at thelarche were modified by other factors associated with early thelarche, including being born in a more recent birth cohort , African-American/Black or Hispanic/Latina identity , lower socioeconomic status , and increased familial risk of breast cancer .
The Sister Study is a prospective cohort designed to investigate environmental and genetic risk factors for breast cancer (for more details, see ). From 2003 to 2009, 50,884 women enrolled in the cohort. Women were eligible if they lived in the USA including Puerto Rico, were between the ages of 35–74 years, and had a sister diagnosed with breast cancer, but were breast cancer-free themselves at enrollment.
Women completed a computer-assisted telephone interview at baseline which included information on demographics, reproductive and lifestyle factors, and medical and family history. Women also completed a self-administered family history questionnaire that included questions about potential maternal, in utero and infancy exposures. We utilized baseline data from Sister Study Data Release 7.2 for this analysis.
All participants provided written informed consent. The institutional review board of the National Institutes of Health approved the study.
Pubertal timing assessment
At the baseline interview, women reported the age in years when they first noticed their breasts developing. Alternatively, women reported their grade in school, which we converted to age (1.2% of the cohort reported grade only). We excluded women who reported that thelarche occurred at age 21 or older, which we considered to be implausible. We categorized timing of thelarche as early (≤ 10 years), average (11–13 years) and late (≥ 14 years) based on the distribution of age at thelarche in the cohort (Additional file 1: Fig. S1). Women also reported their age at menarche, which we categorized as early (≤ 11 years), average (12–13 years) and late (≥ 14 years).
Early-life exposure assessment
We considered participants’ perinatal environment, which included what they may have been exposed to while in utero or during infancy. In utero exposures included mothers’ exposures to pre-pregnancy and pregnancy-related diabetes, pregnancy-related hypertension, pre-eclampsia, eclampsia or toxemia, diethylstilbestrol (DES) use during pregnancy, living or working on a farm during pregnancy, and smoking during pregnancy using four response categories. For all of these, we considered responses of “definitely” and “probably” as exposed and categorized “probably not” and “definitely not” as unexposed. We defined gestational diabetes as a report of pregnancy-related diabetes and no report of pre-pregnancy diabetes, and gestational hypertension as a report of pregnancy-related hypertension and no report of pre-eclampsia, eclampsia, or toxemia. We did not collect information on type of pre-pregnancy diabetes or on pre-pregnancy hypertension. We also considered any diabetes and any gestational hypertensive disorder. Maternal age at the participant’s birth was reported continuously, with categorical options provided if the participant did not know the exact age.
Additional birth- and infancy-related exposures we considered were birthweight, gestational age, multiple gestation, birth order, and type of infant feeding. Participants reported their own birthweight in pounds and ounces. If unknown, they were asked if they weighed more or less than 5lbs at birth. We converted birthweight to grams and categorized it into clinically relevant categories (< 2500 g, 2500–3999 g and ≥ 4000 g). Participants reported whether they were born within one week of their mothers’ due date, and if not, whether they were born less than 2 weeks, 2–4 weeks, 1–2 months, or more than 2 months before or after. We categorized gestational age at birth as born ≥ 1 month before, 2–4 weeks before, or not born ≥ 2 weeks before the due date. Participants reported if they were part of a multiple birth (including stillbirths). We classified participants as firstborn or not based on the birth dates of full siblings and maternal half-siblings ascertained in baseline questionnaires. Participants reported if they were ever breastfed and if they were ever fed soy formula as an infant separately using four response categories, which we dichotomized as described for maternal exposures.
We categorized birth year into approximately 10-year intervals (1928–1939, 1940–1949, 1950–1959 and 1960–1974). Women self-identified their race as American Indian or Alaska Native, Asian, Black or African-American, Native Hawaiian or other Pacific Islander, and/or White. They also reported if they considered their ethnicity to be Hispanic or Latina. We categorized race/ethnicity as non-Hispanic White, non-Hispanic African-American/Black, Hispanic/Latina, and others, which included women who identified as Asian/Pacific Islander, American Indian/Alaska native, or who did not specify race, and did not identify as Hispanic/Latina. Qualitative family income level growing up (well-off, middle income, low income, or poor) and relative weight at age 10 (heavier, same weight as, or lighter than peers) were both reported at enrollment. We also collected detailed information on breast cancer family history, which we used to calculate a continuous Bayesian family history score (BFHS) to assess familial risk. This score was developed in the Sister Study cohort and incorporates family size, number and age at diagnosis of breast cancer cases in first-degree relatives, and current age or age at death for non-cases (for more details, see [12, 13]).
Of the 50,884 women enrolled in the cohort, we excluded 3 women who withdrew their data and 810 women who did not complete the family history questionnaire (Additional file 2: Fig. S2). Since we were interested in in utero exposures, we also excluded women who reported that they were adopted (n = 188). We excluded 609 women with missing age at thelarche (n = 576) or thelarche reported at age 21 or older (n = 33). Lastly, we excluded women with missing data on race/ethnicity and/or childhood family income (n = 112). This left an analytic sample of 49,162 women.
We examined the distributions of demographic and early-life factors by timing of thelarche. We used polytomous logistic regression to estimate odds ratios (ORs) and 95% confidence intervals (CIs) for associations of early-life exposures with early (≤ 10) and late thelarche (≥ 14) relative to average age (11–13 years). We adjusted for birth cohort, race/ethnicity, and childhood family income. We additionally adjusted for relative weight at age 10 to examine whether associations were independent of childhood body size, but we did not conduct a formal mediation analysis due to ambiguity about the relative timing since thelarche ranged from 4 to 20 years. We excluded 129 women with missing data for relative weight at age 10 from these analyses.
We examined whether associations between early-life exposures and timing of thelarche were modified by birth cohort, race/ethnicity, childhood family income and relative weight at age 10 through stratification and tested for statistical heterogeneity using a likelihood ratio test. We estimated stratum-specific associations for non-Hispanic White, non-Hispanic African-American/Black and Hispanic/Latina women only. We examined effect modification by extent of breast cancer family history using the continuous BFHS and also stratified by BFHS, dichotomized at the median.
We examined alternative modeling strategies for age at thelarche in sensitivity analyses. We considered age ≥ 13 years as late versus a referent group of 11–12 years. We categorized age at thelarche in 7 groups (≤ 9, 10, 11, 12 (referent), 13, 14 and ≥ 15 years) to explore associations with very early or very late thelarche. We also examined age at thelarche as a continuous outcome using linear regression to quantify the difference in years between exposure groups.
The proportion of missing data for early-life exposures in analyses using the entire sample ranged from < 0.1% for multiple birth to about 25% for gestational hypertensive disorders and birthweight. Gestational age at birth was missing for > 50%. Therefore, we also conducted multiple imputation analyses for all early-life exposures under the assumption that data were missing at random, conditional on the specified covariates. The imputation models included the outcome, all early-life exposures, all covariates, age at menarche, and whether the participant’s mother was alive at baseline, which was a predictor of missing early-life exposure data. We used chained equations to generate 50 imputed datasets. All participants were included in the imputation models, but analysis models were restricted to the 49,162 eligible women (Additional file 2: Fig. S2). We then ran three sets of adjusted models for early and late thelarche in the imputed datasets and combined effect estimates across datasets using Rubin’s rules . Model 1 included birth cohort, race/ethnicity and childhood family income to match the complete case analysis. Model 2 additionally adjusted for maternal age and firstborn status. Model 3 mutually adjusted for early-life exposures based on a directed acyclic graph (Additional file 3: Fig. S3), with different adjustment sets for each early-life exposure.
We conducted sensitivity analyses restricted to women less than 60 years at baseline, under the hypothesis that reporting errors were likely greater for older women. In separate analyses, we restricted to women whose mothers were alive at baseline, allowing participants to potentially consult their mothers about early-life exposures, which may have improved accuracy. We excluded women who reported thelarche before age 8 years or at age 16 or later in sensitivity analyses to examine whether these extremes were driving the primary associations that we observed. Since age at menarche is correlated with age at thelarche (r = 0.6), but may be more accurately reported, we ran complementary analyses examining associations between early-life exposures and timing of menarche. We also examined associations with early thelarche (≤ 10 years) and/or early menarche (≤ 11 years) relative to experiencing neither event at an early age under the hypothesis, based on the correlation between ages at thelarche and menarche, that women who reported both events at an early age may have been more accurate in their recall of early pubertal onset than women who reported early thelarche or early menarche only. Women who reported early thelarche only have a longer time from thelarche to menarche, or pubertal tempo, and women with early menarche only have a shorter tempo, compared with women with both early thelarche and menarche. In the context of our data, relatively long or short tempo may indicate error in the recall of age at thelarche, but could also reflect true differences in tempo, which may also be biologically relevant for breast cancer risk .
We conducted all analyses using SAS 9.4 (SAS Institute Inc, Cary, NC).
The average age at thelarche was 12.2 years (median: 12, range: 4–20). Approximately 97% of women reported that thelarche occurred between ages 8 and 15 years, while < 0.1% reported thelarche before 8 years of age and 3% reported thelarche at age 16 or later. Early thelarche (≤ 10 years) was more common in non-Hispanic African-American/Black and Hispanic/Latina women, those born after 1960, and those who grew up in a poor household (Table 1).
Early thelarche was associated with multiple pre- and postnatal exposures, while few associations were observed with late thelarche (Table 2). Maternal gestational hypertensive disorders, DES use, maternal smoking during pregnancy and having a teenage mother were each associated with a 20–30% increased odds of early thelarche in daughters. Maternal diabetes prior to pregnancy was associated with more than a 70% increased likelihood of early thelarche, but there was no association between gestational diabetes and early thelarche. Being firstborn was positively associated with early thelarche and inversely associated with late thelarche, while the opposite pattern was observed for being part of a multiple birth. Preterm birth (born ≥ 1 month before due date) was also positively associated with late thelarche. Low birthweight (< 2500 g) was positively associated with early and late thelarche relative to average birthweight (2500–3499 g), while no associations were observed for high birthweight (≥ 4000 g). A similar U-shaped pattern was observed for soy formula in infancy. Being breastfed in infancy was not associated with early thelarche, though we observed a minor decrease in the odds of late thelarche.
Associations were similar in models adjusted for relative weight at 10 years of age, except for birthweight (Additional file 4: Table S1). Adjusting for relative weight, low birthweight was associated with early (OR = 1.16, 95% CI 1.05–1.28), but not late (OR = 1.03, 95% CI 0.94–1.13) thelarche. In addition, high birthweight was inversely associated with early (OR = 0.90, 95% CI 0.81–1.00) and positively associated with late (OR = 1.09, 95% CI 0.99–1.21) thelarche. Patterns were similar within strata of childhood weight (Additional file 5: Table S2, birthweight p for heterogeneity by childhood weight = 0.99).
Patterns of association were similar across strata of birth cohort (Additional file 6: Table S3), race/ethnicity (Additional file 7: Table S4), childhood family income (Additional file 8: Table S5) and extent of breast cancer family history (Additional file 9: Table S6). The positive association of soy formula in infancy with early thelarche was only observed among women born in 1960–1974 (OR = 1.34, 95% CI 1.03–1.74), non-Hispanic African-American/Black women (OR = 1.63, 95% CI 1.02–2.60) and women who grew up in a poor family (OR = 1.70, 95% CI 1.00–2.90), though the interaction was statistically significant for childhood family income only (p = 0.02).
Results were similar when thelarche at 11–12 years was used as the referent group (data not shown). Associations were generally stronger in magnitude when we considered very early thelarche (≤ 9 years) (Additional file 10: Table S7). U-shaped associations of low birthweight and soy formula with age at thelarche were more prominent in the model that included 7 thelarche categories. The inference for most early-life exposures and timing of thelarche was similar when age at thelarche was modeled continuously using linear regression (Additional file 10: Table S7). Exceptions include DES use, which was not associated with thelarche when modeled continuously, along with low birthweight and soy formula, which were positively associated with both early and late thelarche in the polytomous models.
Results were nearly identical in multiple imputation analyses (Additional file 11: Table S8). The inference also was unchanged in analyses limited to either women younger than 60 years or women whose mother was still living at baseline (data not shown), except that pre-pregnancy diabetes was no longer associated with early thelarche after excluding women whose mother was deceased at baseline. Results were similar for all exposures in sensitivity analyses excluding women with extremely early (< 8 years) or late (≥ 16 years) thelarche (data not shown). Patterns were similar when we examined early-life exposures in relation to age at menarche as a marker of pubertal timing instead of thelarche (Additional file 12: Table S9). Associations of early-life exposures with early thelarche and early menarche were generally stronger in magnitude than associations with early thelarche or early menarche only, except for birthweight and gestational age (Additional file 13: Table S10).
Multiple pre- and postnatal exposures were associated with early thelarche in a diverse, nationwide cohort of women with a family history of breast cancer. Associations did not meaningfully vary by birth cohort, race/ethnicity, socioeconomic status, or extent of breast cancer family history. Our findings support the hypothesis that the early-life environment influences the timing of pubertal breast development, especially in sub-groups who experience differential burdens of early thelarche.
Maternal pre-pregnancy obesity is a risk factor for developing gestational hypertensive disorders in pregnancy  and has also been associated with earlier thelarche in daughters in contemporary cohorts [16, 17]. We did not collect data on maternal pre-pregnancy body mass index (BMI), which may underlie the observed associations of gestational hypertensive disorders and maternal pre-pregnancy diabetes with earlier thelarche. In the Danish National Birth Cohort (DNBC), crude differences in mean age at thelarche in daughters of women with gestational hypertensive disorders compared to daughters of women with normotensive pregnancies were attenuated after adjustment for maternal pre-pregnancy BMI and other factors . In contrast, a Norwegian case–control study found that daughters exposed to pre-eclamptic pregnancies were less likely to experience thelarche by 10.8 years of age than daughters of normotensive mothers, independent of maternal BMI, but only among exclusively breastfed girls .
We did not observe an association between gestational diabetes and age at thelarche, consistent with two prospective studies of girls enrolled in the Kaiser Permanente Northern California (KPNC) health system [17, 20]. In DNBC, there was no difference in mean age at thelarche in daughters of women with gestational diabetes, type 1 diabetes or type 2 diabetes after adjustment for maternal confounders, including pre-pregnancy BMI . A prior, small study (n = 310 girls) within the DNBC found that daughters of women with gestational diabetes experienced earlier thelarche than controls, but did not adjust for maternal confounders .
We found that women exposed in utero to DES, a potent synthetic estrogen, were more likely to experience early thelarche. Earlier vaginal opening, an estrogen-mediated marker of pubertal onset analogous to thelarche in humans [23, 24], has been observed in rodents exposed to DES during gestation . A study of 30 DES-exposed daughters and 30 controls found no difference in mean age at thelarche associated with DES . While strengths of that study were the use of medical record-confirmed history of prenatal DES exposure and shorter recall time for age at thelarche (recalled at ages 17–30), the small sample size, women with abnormal Pap smears as controls, and lack of control for confounding could explain the lack of association with age at thelarche. We did not observe an association when age at thelarche was modeled as a continuous outcome. This is in line with previous studies, including in our cohort and a cohort with record-confirmed DES exposure, that observed an increased risk of very early menarche (≤ 10 years) in DES daughters [27, 28], while others did not observe a difference in mean age at menarche [26, 29, 30].
Women who were fed soy formula in infancy, which includes high concentrations of phytoestrogens, including genistein [31, 32], were more likely to experience very early and very late thelarche. The effects of phytoestrogens on reproductive development in animal and human studies have varied by timing and dose of exposure . Experimental evidence in mice has observed opposing effects on pubertal onset associated with neonatal genistein administration: mice administered low-dose genistein had earlier vaginal opening, while those administered a high dose had later opening . Three small prospective studies of girls fed soy formula in infancy did not observe differences in breast bud volume  or timing of pubertal breast development [36, 37] compared with those fed cow’s milk formula or breastmilk. The association we observed with early thelarche was specific to African-American/Black women and those who grew up in poor households, two groups at increased risk of early thelarche [4, 9]. Our results may be explained by residual confounding, as families who choose soy formula may differ in other ways that affect timing of thelarche. We did not observe later thelarche in women who were breastfed in infancy, as has been observed in some [38,39,40], but not all , prospective cohorts.
Higher in utero estrogen exposure also may explain the earlier age at thelarche we observed in firstborn daughters, as maternal estrogens are higher in first compared to subsequent full-term pregnancies . Higher cord blood estrogen concentrations have also been observed in firstborn compared with later born children . Being firstborn was associated with earlier thelarche in the Avon Longitudinal Study of Parents and Children (ALSPAC) cohort  and earlier pubarche, but not thelarche, in the Hong Kong Children of 1997 birth cohort . We also observed earlier thelarche in daughters of teenage mothers, who are more likely to be firstborn, though these associations were independent of one another.
While cigarette smoke is thought to be anti-estrogenic, it includes thousands of chemicals, including reproductive and developmental toxicants and endocrine disruptors, that may affect pubertal timing . Although rates of smoking during pregnancy have decreased in the USA in more recent birth cohorts , smoking during pregnancy is still prevalent in many countries . About one-third of the women in our cohort reported that their mother smoked during pregnancy, which was associated with earlier thelarche. Two studies conducted in prospective European cohorts, in which approximately 20–30% of girls were exposed to maternal smoking during pregnancy, also observed associations with earlier thelarche [44, 49]. In a US cohort of girls born in the late 1990s in which < 10% were exposed to prenatal smoke, no association was observed overall with age at thelarche .
Low birthweight was associated with early and late thelarche, while being born more than a month early and being part of a multiple gestation, conditions associated with low birthweight, were both associated with later thelarche. Findings from previous studies examining birthweight, size for gestational age and/or preterm birth with age at thelarche have been inconsistent [44, 51,52,53,54,55,56,57,58,59,60]. High birthweight is associated with childhood obesity , a risk factor for early thelarche . In our data, women with high birthweight were more likely to report that they were heavier than their peers at age 10, while women with low birthweight were more likely to report that they were lighter than their peers; relative weight at age 10 was inversely associated with age at thelarche (data not shown). However, low birthweight infants are more likely to experience rapid postnatal growth , which is also associated with earlier thelarche [44, 60]. We hypothesize that the U-shaped association that we observed overall with low birthweight may reflect modification by postnatal growth patterns. Postnatal growth may also explain the change in the association between birthweight and age at thelarche when we controlled for childhood body size by adjustment or stratification. High birthweight babies may regress toward the mean after birth through slower or catch-down growth . While we do not have data to examine the influence of postnatal growth directly, our finding that low birthweight was positively associated with early thelarche while high birthweight was associated with late thelarche in models stratified by childhood body size suggest that, among girls of similar body size at age 10, those that grew more rapidly between birth and age 10 experienced earlier thelarche, while those that grew more slowly between birth and age 10 experienced later thelarche. Alternatively, other factors that influence fetal growth could underlie the associations we observed between birthweight and age at thelarche.
The average age at thelarche of 12 years in our cohort was about a year later than what has been reported in prospective studies of women born around the same time . The distribution of age at thelarche in our cohort was slightly right-skewed, which also suggests that women in our cohort may have recalled a later age at thelarche than when it truly occurred. While some misreporting of recalled age at thelarche is likely, categorizing age at thelarche as early, average and late may have minimized measurement error, as has been observed for age at menarche . The prevalence of early thelarche increased in successive birth cohorts and early thelarche was more common in Black and Hispanic women. These demographic differences are consistent with prospective thelarche data [4, 6], suggesting that our recalled measure likely captured women who experienced thelarche relatively early compared to their peers, even if there was error in the recall of the absolute age. Associations of early-life exposures with early and late age at menarche, which previous studies have shown is reliably reported into adulthood  and is correlated with age at thelarche , were similar to the associations we observed with early and late thelarche, which suggests that measurement error in recalled age at thelarche is unlikely to explain our findings. In addition, associations were generally stronger in magnitude for women who reported both early thelarche and early menarche, suggesting that misreporting of age at thelarche may have biased the results of our primary analyses of early thelarche toward the null. An alternate interpretation of this analysis is that stronger associations of early-life exposures with early ages at thelarche and menarche, compared with associations of early-life exposures with early thelarche without early menarche, reflect an association of these exposures with shorter pubertal tempo. However, potential measurement error in addition to imprecision in the assessment of ages at both thelarche and menarche, recalled to the nearest year, makes it difficult to accurately assess pubertal tempo using retrospective data, so it is not clear the extent to which this analysis captures true differences in tempo.
Strengths of this study include the large sample size and wide range of pre- and postnatal exposures. We were able to examine past exposures that are no longer used at all or as frequently, such as DES use and smoking during pregnancy, but are informative for current exposures to endocrine-disrupting chemicals . We were limited by recalled data on early-life exposures, which may be reported with error. Participants were provided with a prepaid phone card and encouraged to contact their mothers or other relatives for assistance in completing the early-life exposure information, but we do not know how many women did. In a validation study, a sample of 1,800 mothers of participants under 60 years of age at enrollment completed a similar questionnaire on pregnancy-related factors. Agreement between daughter’s and mother’s report was good for most exposures, with kappas ranging from 0.6 (pre-eclampsia) to 0.9 (birth order, maternal age).
Our results may be subject to confounding by other unmeasured factors such as pre-pregnancy BMI, gestational weight gain, and genetic influences, as well as residual confounding or variation by socioeconomic factors. While we consider the diversity of our cohort to be a strength, we had reduced precision in stratified analyses in some groups, such as racial/ethnic minorities. Women in our cohort have at least one sister with breast cancer, and have, on average, approximately twice the risk of breast cancer as women without a first-degree family history . While we observed no differences by extent of familial risk, our results may not be generalizable to women without a family history of breast cancer. Nonetheless, it is important to examine risk factors for early thelarche, a breast cancer risk factor, among women at increased risk of breast cancer due to their family history as these women may derive the most benefit from early-life interventions to reduce their lifetime risk of breast cancer.
Our findings suggest that the early-life environment influences breast development and may influence the risk of breast cancer by altering the timing of pubertal onset. Our results also support the hypothesis that environmental factors acting early in life, including maternal pregnancy complications and exposure to endocrine-disrupting chemicals, contribute to the secular decline in age at thelarche, which may lead to future increases in breast cancer incidence.
Availability of data and materials
Requests for data, including the data used in this manuscript, are welcome. De-identified data are made available upon request as described on the study website (https://sisterstudy.niehs.nih.gov/English/data-requests.htm). The data sharing policy was developed to protect the privacy of study participants and is consistent with study informed consent documents as approved by the NIEHS Institutional Review Board.
Bayesian family history score
Body mass index
Collaborative Group on Hormonal Factors in Breast Cancer. Menarche, menopause, and breast cancer risk: individual participant meta-analysis, including 118 964 women with breast cancer from 117 epidemiological studies. Lancet Oncol. 2012;13(11):1141–51.
Bodicoat DH, Schoemaker MJ, Jones ME, McFadden E, Griffin J, Ashworth A, et al. Timing of pubertal stages and breast cancer risk: the Breakthrough Generations Study. Breast Cancer Res. 2014;16(1):R18.
Goldberg M, D’Aloisio AA, O’Brien KM, Zhao S, Sandler DP. Pubertal timing and breast cancer risk in the Sister Study cohort. Breast Cancer Res. 2020;22(1):1–11.
Biro FM, Greenspan LC, Galvez MP, Pinney SM, Teitelbaum S, Windham GC, et al. Onset of breast development in a longitudinal cohort. Pediatrics. 2013;132(6):1019–27.
Brix N, Ernst A, Lauridsen LLB, Parner ET, Arah OA, Olsen J, et al. Childhood overweight and obesity and timing of puberty in boys and girls: cohort and sibling-matched analyses. Int J Epidemiol. 2020;49(3):834–44.
Eckert-Lind C, Busch AS, Petersen JH, Biro FM, Butler G, Bräuner EV, et al. Worldwide secular trends in age at pubertal onset assessed by breast development among girls: a systematic review and meta-analysis. JAMA Pediatr. 2020;174(4):1–11.
Lee Y, Styne D. Influences on the onset and tempo of puberty in human beings and implications for adolescent psychological development. Horm Behav. 2013;64(2):250–61.
Parent AS, Teilmann G, Juul A, Skakkebaek NE, Toppari J, Bourguignon JP. The timing of normal puberty and the age limits of sexual precocity: variations around the world, secular trends, and changes after migration. Endocr Rev. 2003;24(5):668–93.
Hiatt RA, Stewart SL, Hoeft KS, Kushi LH, Windham GC, Biro FM, et al. Childhood socioeconomic position and pubertal onset in a cohort of multiethnic girls: implications for breast cancer. Cancer Epidemiol Biomarkers Prev. 2017;26(12):1714–21.
Terry MB, Keegan THM, Houghton LC, Goldberg M, Andrulis IL, Daly MB, et al. Pubertal development in girls by breast cancer family history: the LEGACY girls cohort. Breast Cancer Res. 2017;19(1):69.
Sandler DP, Hodgson ME, Deming-Halverson SL, Juras PS, D’Aloisio AA, Suarez LM, et al. The Sister Study cohort: baseline methods and participant characteristics. Environ Health Perspect. 2017;125(12):127003.
Jiang Y, Weinberg CR, Sandler DP, Zhao S. Use of detailed family history data to improve risk prediction, with application to breast cancer screening. PLOS ONE. 2019;14(12):e0226407.
Niehoff NM, Nichols HB, Zhao S, White AJ, Sandler DP. Adult physical activity and breast cancer risk in women with a family history of breast cancer. Cancer Epidemiol Biomarkers Prev. 2019;28(1):51–8.
Rubin DB. Multiple imputation for nonresponse in surveys. New York: John Wiley & Sons; 1987.
Booker WA. Hypertensive disorders of pregnancy. Clin Perinatol. 2020;47(4):817–33.
Lawn RB, Lawlor DA, Fraser A. Associations between maternal prepregnancy body mass index and gestational weight gain and daughter’s age at menarche. Am J Epidemiol. 2018;187(4):677–86.
Kubo A, Deardorff J, Laurent CA, Ferrara A, Greenspan LC, Quesenberry CP, et al. Associations between maternal obesity and pregnancy hyperglycemia and timing of pubertal onset in adolescent girls: a population-based study. Am J Epidemiol. 2018;187(7):1362–9.
Lunddorf LLH, Brix N, Ernst A, Arendt LH, Støvring H, Clemmensen PJ, et al. Hypertensive disorders in pregnancy and timing of pubertal development in daughters and sons. Hum Reprod. 2020;35(9):2124–33.
Schraw JM, Øgland B, Dong YQ, Nilsen ST, Forman MR, Ogland B, et al. In utero preeclampsia exposure, milk intake and pubertal development. Reprod Toxicol. 2015;54:19–25.
Kubo A, Ferrara A, Laurent CA, Windham GC, Greenspan LC, Deardorff J, et al. Associations between maternal pregravid obesity and gestational diabetes and the timing of pubarche in daughters. Am J Epidemiol. 2016;184(1):7–14.
Lauridsen LLB, Arendt LH, Ernst A, Brix N, Parner ET, Olsen J, et al. Maternal diabetes mellitus and timing of pubertal development in daughters and sons: a nationwide cohort study. Fertil Steril. 2018;110(1):35–44.
Grunnet LG, Hansen S, Hjort L, Madsen CM, Kampmann FB, Thuesen ACB, et al. Adiposity, dysmetabolic traits, and earlier onset of female puberty in adolescent offspring of women with gestational diabetes mellitus: a clinical study within the Danish national birth cohort. Diabetes Care. 2017;40(12):1746–55.
Buck Louis GM, Gray LE, Marcus M, Ojeda SR, Pescovitz OH, Witchel SF, et al. Environmental factors and puberty timing: expert panel research needs. Pediatrics. 2008;121(Suppl 3):192.
Soto AM, Rubin BS, Sonnenschein C. Endocrine disruption and the female. In: Gore AC, editor. Endocrine-disrupting chemicals: from basic research to clinical practice. 1st ed. Humana Press; 2007. p. 9–31.
Franssen D, Ioannou YS, Alvarez-real A, Gerard A, Mueller JK, Heger S, et al. Pubertal timing after neonatal diethylstilbestrol exposure in female rats: neuroendocrine vs peripheral effects and additive role of prenatal food restriction. Reprod Toxicol. 2014;44:63–72.
Meyer-Bahlburg HF, Ehrhardt AA, Rosen LR, Feldman JF, Veridiano NP, Zimmerman I, et al. Psychosexual milestones in women prenatally exposed to diethylstilbestrol. Horm Behav. 1984;18(3):359–66.
D’Aloisio AA, DeRoo LA, Baird DD, Weinberg CR, Sandler DP. Prenatal and infant exposures and age at menarche. Epidemiology. 2013;24(2):277–84.
Hatch EE, Troisi R, Wise LA, Titus-Ernstoff L, Hyer M, Palmer JR, et al. Preterm birth, fetal growth, and age at menarche among women exposed prenatally to diethylstilbestrol (DES). Reprod Toxicol. 2011;31(2):151–7.
Bibbo M, Gill WB, Azizi F, Blough R, Fang VS, Rosenfield RL, et al. Follow-up study of male and female offspring of DES-exposed mothers. Obs Gynecol. 1977;49(1):1–8.
Barnes AB. Menstrual history of young women exposed in utero to diethylstilbestrol. Fertil Steril. 1979;32(2):148–53.
Setchell KDR, Zimmer-Nechemias L, Cai J, Heubi JE. Exposure of infants to phyto-oestrogens from soy-based infant formula. Lancet. 1997;350(9070):23–7.
Cao Y, Calafat AM, Doerge DR, Umbach DM, Bernbaum JC, Twaddle NC, et al. Isoflavones in urine, saliva, and blood of infants: data from a pilot study on the estrogenic activity of soy formula. J Expo Sci Environ Epidemiol. 2009;19(2):223–34.
Jefferson WN, Patisaul HB, Williams CJ. Reproductive consequences of developmental phytoestrogen exposure. Reproduction. 2012;143(3):247–60.
Jefferson WN, Padilla-Banks E, Newbold RR. Adverse effects on female development and reproduction in CD-1 mice following neonatal exposure to the phytoestrogen genistein at environmentally relevant doses. Biol Reprod. 2005;73(4):798–806.
Andres A, Moore MB, Linam LE, Casey PH, Cleves MA, Badger TM. Compared with feeding infants breast milk or cow-milk formula, soy formula feeding does not affect subsequent reproductive organ size at 5 years of age. J Nutr. 2015;145(5):871–5.
Sinai T, Ben-Avraham S, Guelmann-Mizrahi I, Goldberg MR, Naugolni L, Askapa G, et al. Consumption of soy-based infant formula is not associated with early onset of puberty. Eur J Nutr. 2019;58(2):681–7.
Strom BL, Schinnar R, Ziegler EE, Barnhart KT, Sammel MD, Macones GA, et al. Exposure to soy-based formula in infancy and endocrinological and reproductive outcomes in young adulthood. JAMA. 2001;286(7):807–14.
Kale A, Deardorff J, Lahiff M, Laurent C, Greenspan LC, Hiatt RA, et al. Breastfeeding versus formula-feeding and girls’ pubertal development. Matern Child Health J. 2014;19(3):519–27.
Aghaee S, Deardorff J, Greenspan LC, Quesenberry CP, Kushi LH, Kubo A. Breastfeeding and timing of pubertal onset in girls: a multiethnic population-based prospective cohort study. BMC Pediatr. 2019;19(1):277.
Lee HA, Kim YJ, Lee H, Gwak HS, Hong YS, Kim HS, et al. The preventive effect of breast-feeding for longer than 6 months on early pubertal development among children aged 7–9 years in Korea. Public Health Nutr. 2015;18(18):3300–7.
Kwok MK, Leung GM, Lam TH, Schooling CM. Breastfeeding, childhood milk consumption, and onset of puberty. Pediatrics. 2012;130(3):e631–9.
Panagiotopoulou K, Katsouyanni K, Petridou E, Garas Y, Tzonou A, Trichopoulos D. Maternal age, parity, and pregnancy estrogens. Cancer Causes Control. 1990;1(2):119–24.
Maccoby EE, Doering CH, Jacklin CN, Kraemer H. Concentrations of sex hormones in umbilical-cord blood: their relation to sex and birth order of infants. Child Dev. 1979;50(3):632–42.
Maisonet M, Christensen KY, Rubin C, Holmes A, Flanders WD, Heron J, et al. Role of prenatal characteristics and early growth on pubertal attainment of British girls. Pediatrics. 2010;126(3):e591-600.
Kwok MK, Leung GM, Schooling CM. Associations of birth order with early adolescent growth, pubertal onset, blood pressure and size: evidence from Hong Kong’s “Children of 1997” Birth Cohort. PLoS One. 2016;11(4):e0153787.
Centers for Disease Control and Prevention (US), National Center for Chronic Disease Prevention and Health Promotion (US), Office on Smoking and Health (US). Chapter 8. Reproductive and Developmental Effects. In: How Tobacco Smoke Causes Disease: The Biology and Behavioral Basis for Smoking-Attributable Disease: A Report of the Surgeon General. Atlanta, GA: U.S. Department of Health and Human Services; 2010. p. 521–644.
Cnattingius S. The epidemiology of smoking during pregnancy: Smoking prevalence, maternal characteristics, and pregnancy outcomes. Nicotine Tob Res. 2004;6(Suppl 2):125–40.
Lange S, Probst C, Rehm J, Popova S. National, regional, and global prevalence of smoking during pregnancy in the general population: a systematic review and meta-analysis. Lancet Glob Heal. 2018;6(7):e769–76.
Brix N, Ernst A, Lauridsen LLB, Parner ET, Olsen J, Henriksen TB, et al. Maternal smoking during pregnancy and timing of puberty in sons and daughters: a population-based cohort study. Am J Epidemiol. 2019;188(1):47–56.
Windham GC, Lum R, Voss R, Wolff M, Pinney SM, Teteilbaum SL, et al. Age at pubertal onset in girls and tobacco smoke exposure during pre- and postnatal susceptibility windows. Epidemiology. 2017;28(5):719–27.
Powls A, Botting N, Cooke RWI, Pilling D, Marlow N. Growth impairment in very low birthweight children at 12 years: correlation with perinatal and outcome variables. Arch Dis Child Fetal Neonatal Ed. 1996;75(3):152–7.
James E, Wood CL, Nair H, Williams TC. Preterm birth and the timing of puberty: a systematic review. BMC Pediatr. 2018;18(1):3.
Semiz S, Kurt F, Kurt DT, Zencir M, Sevinç Ö. Factors affecting onset of puberty in Denizli province in Turkey. Turk J Pediatr. 2009;51(1):49–55.
Olivo-Marston S, Graubard BI, Visvanathan K, Forman MR. Gender-specific differences in birthweight and the odds of puberty: NHANES III, 1988–94. Paediatr Perinat Epidemiol. 2010;24(3):222–31.
Papadimitriou A, Kanakis G, Douros K, Papadimitriou DT, Boutsiadis AH, Nicolaidou P, et al. Constitutional advancement of growth is associated with early puberty in girls. Horm Res Paediatr. 2011;76(4):273–7.
Hvidt JJ, Brix N, Ernst A, Braskhøj-Lauridsen LL, Ramlau-Hansen CH. Size at birth, infant growth, and age at pubertal development in boys and girls. Clin Epidemiol. 2019;11:873–83.
Hui LL, Leung GM, Wong M-YY, Lam TH, Schooling CM. Small for gestational age and age at puberty: evidence from Hong Kong’s “Children of 1997” birth cohort. Am J Epidemiol. 2012;176(9):785–93.
Bhargava SKK, Ramji S, Srivastava U, Sachdev HPP, Kapani V, Datta V, et al. Growth and sexual maturation of low birth weight children: a 14 year follow up. Indian Pediatr. 1995;32(9):963–70.
Ghirri P, Bernardini M, Vuerich M, Cuttano AM, Coccoli L, Merusi I, et al. Adrenarche, pubertal development, age at menarche and final height of full-term, born small for gestational age (SGA) girls. Gynecol Endocrinol. 2001;15(2):91–7.
Wang Y, Dinse GE, Rogan WJ. Birth weight, early weight gain and pubertal maturation: a longitudinal study. Pediatr Obes. 2012;7(2):101–9.
Terry MB, Wei Y, Esserman D, McKeague IW, Susser E. Pre- and postnatal determinants of childhood body size: cohort and sibling analyses. J Dev Orig Health Dis. 2011;2(02):99–111.
Weaver LT. Rapid growth in infancy: balancing the interests of the child. J Pediatr Gastroenterol Nutr. 2006;43(4):428–32.
Atladottir H, Thorsdottir I. Energy intake and growth of infants in Iceland—a population with high frequency of breast-feeding and high birth weight. Eur J Clin Nutr. 2000;54(9):695–701.
Biro FM, Pajak A, Wolff MS, Pinney SM, Windham GC, Galvez MP, et al. Age of menarche in a longitudinal US Cohort. J Pediatr Adolesc Gynecol. 2018;31(4):339–45.
Cooper R, Blell M, Hardy R, Black S, Pollard TM, Wadsworth MEJ, et al. Validity of age at menarche self-reported in adulthood. J Epidemiol Community Health. 2006;60(11):993–7.
Must A, Phillips SM, Naumova EN, Blum M, Harris S, Dawson-Hughes B, et al. Recall of early menstrual history and menarcheal body size: after 30 years, how well do women remember? Am J Epidemiol. 2002;155(7):672–9.
Fenton SE. Endocrine-disrupting compounds and mammary gland development: early exposure and later life consequences. Endocrinology. 2006;147(6 Suppl):S18-24.
Collaborative Group on Hormonal Factors in Breast Cancer. Familial breast cancer: collaborative reanalysis of individual data from 52 epidemiological studies including 58 209 women with breast cancer and 101 986 women without the disease. Lancet. 2001;358(9291):1389–99.
Open Access funding provided by the National Institutes of Health (NIH). This work was supported by the Intramural Research Program of the National Institutes of Health, National Institute of Environmental Health Sciences (Z01-ES044005 to DPS).
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. Distribution of age at thelarche in the analytic sample
. Flowchart of Sister Study participants included in analytic sample
. Directed acyclic graph of hypothesized associations between early-life exposures and age at thelarche
. Associations between early-life exposures and timing of thelarche in the Sister Study cohort additionally adjusted for relative weight at age 10 (N = 49,033)
. Associations between early-life exposures and timing of thelarche in the Sister Study cohort by relative weight at age 10 (N = 49,033)
. Associations between early-life exposures and timing of thelarche in the Sister Study cohort by birth cohort (N = 49,162)
. Associations between early-life exposures and timing of thelarche in the Sister Study cohort by race/ethnicity (N = 47,883)
. Associations between early-life exposures and timing of thelarche in the Sister Study cohort by qualitative childhood family income (N = 49,162)
. Associations between early-life exposures and timing of thelarche in the Sister Study cohort by Bayesian family history score (BFHS) (N = 49,151)
. Associations between early-life exposures and age at thelarche using alternate characterizations of age at thelarche in the Sister Study cohort (N = 49,162)
. Associations between early-life exposures and timing of thelarche in the Sister Study cohort with multiple imputation of missing early-life exposure data (N = 49,162)
. Associations between early-life exposures and timing of menarche in the Sister Study cohort (N = 49,130)
. Associations between early-life exposures and early thelarche (≤ 10 years) and/or early menarche (≤ 11 years) in the Sister Study cohort (N = 49,130)
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Goldberg, M., D’Aloisio, A.A., O’Brien, K.M. et al. Early-life exposures and age at thelarche in the Sister Study cohort. Breast Cancer Res 23, 111 (2021). https://doi.org/10.1186/s13058-021-01490-z
- Breast development
- Prenatal exposures