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We examined prospectively the association between weight change during adulthood and breast cancer risk, using data on 1358 incident cases that developed during 5.8 years of follow-up among 40429 premenopausal and 57923 postmenopausal women from six European countries, taking part in the European prospective investigation into cancer and nutrition study. Multivariate Cox regression models were used to calculate hazard ratios according to weight change (kg), defined as the weight difference between age at enrolment and age 20 adjusted for other risk factors. Changes in weight were not associated with premenopausal breast cancer risk. In postmenopausal women, weight gain was positively associated with breast cancer risk only among noncurrent hormone replacement therapy (HRT) users (P-trend 0.0002). Compared to women with a stable weight (±2kg), the relative risk for women who gained 15–20kg was 1.50 (95% confidence interval (CI) 1.06–2.13). The pooled RR per weight gain increment of 5kg was 1.08 (95% CI 1.04–1.12). Weight gain was not associated with breast cancer risk in current HRT users, although, overall, these women experienced a much higher risk of breast cancer compared with nonusers. Our findings suggest that large adult weight gain was a significant predictor of breast cancer in postmenopausal women not taking exogenous hormones.
Weight gain during adult life, body weight, and fat distribution may separately or in combination play a role in the development and prognosis of breast cancer. The association between weight change and breast cancer risk is modified by menopausal status, with higher weight gain associated with decreased risk for premenopausal women and increased risk for postmenopausal women (IARC working group, 2002). More specifically, for postmenopausal breast cancer risk, the most consistent body size predictor appears to be weight gain, even in studies in which general adiposity was only weakly associated with risk (Ziegler, 1997; Ballard-Barbash, 1999; Friedenreich, 2001; Willett, 2001). Adult weight change is considered a dynamic body measure unlike static measures such as body mass index (BMI), and has been hypothesised to better reflect age-related metabolic changes that may be important in breast cancer development (Ballard-Barbash, 1999). Relative risks between 1.2 and 2.3 for the highest vs lowest categories for weight gained between age 18 or 20 and the reference age were reported in previous case–control and cohort studies (Friedenreich, 2001; IARC working group, 2002). However, the data on weight change and breast cancer risk from prospective studies are sparse, especially among premenopausal women. Moreover, the potential effect modification by body size at young adult age (Barnes-Josiah et al, 1995; Huang et al, 1997; Magnusson et al, 1998; Weiderpass et al, 2004) or hormone replacement therapy (HRT) use (Huang et al, 1997; Friedenreich et al, 2002; Morimoto et al, 2002; Lahmann et al, 2003; Feigelson et al, 2004) on the association between weight change and breast cancer risk has been only investigated in a limited number of studies.
The purpose of this study was to examine the association between long-term adult weight change and risk of breast cancer in pre- and postmenopausal women, controlling for other known risk factors in female study participants from the European Prospective Investigation into Cancer and Nutrition (EPIC). A secondary aim of this study was to evaluate whether the association between weight change and risk of breast cancer is modified by (a) initial weight or BMI at age 20, and (b) current HRT use among postmenopausal women.
The EPIC is a multi-centre prospective cohort study designed primarily to investigate the association between nutrition and cancer. The EPIC cohort consists of 23 subcohorts in 10 European countries: Denmark, France, Germany, Greece, Italy, The Netherlands, Norway, Spain, Sweden, and the United Kingdom, thereby allowing comparisons of lifestyle and food habits among regions with very different cancer rates. Food-related and lifestyle questionnaires were administered and anthropometric measurements obtained from all participants at the time of enrolment (1992–2000). The 366521 eligible female participants were mostly aged 25–70 years and recruited from the general population residing in a given geographical area, such as a town or a province (Riboli et al, 2002). Exceptions were the French cohort (health insurance scheme for school employees), the Utrecht cohort in the Netherlands (breast cancer screening attendees), the Ragusa cohort in Italy (blood donors and their spouses), and the Oxford cohort in the UK (based on vegetarian volunteers and healthy eaters). Eligible subjects were invited to participate in the study, and those who accepted gave informed consent and completed questionnaires on their diet, lifestyle and medical history. Study subjects were then invited to a centre to provide a blood sample and to have anthropometric measurements taken, methods of which have been reported in full elsewhere (Riboli and Kaaks, 1997; Riboli et al, 2002).
The present study was based on data from 345365 female participants after excluding women with prevalent cancer at any site at baseline examination, and those with missing nondietary questionnaire data. The study population was further restricted to 125233 women from Denmark, Germany (Potsdam), Greece, Italy (Varese), Sweden (Malmö), and the United Kingdom, with available data on recalled body weight at age 20 or 25 years, and measured or predicted (Oxford, ‘health conscious group') anthropometric characteristics at study enrolment. Women were classified according to menopausal status at enrolment based on an algorithm as described elsewhere (Lahmann et al, 2004). Accordingly, 33.1% of women were classified as premenopausal and 47.7% were naturally postmenopausal. Women who were perimenopausal (11.4%) or had a surgical menopause or uncertain menopausal status (7.8%) were excluded from the present analysis. Subjects with missing data on measured anthropometric characteristics at enrolment and recalled weight at age 20, and women aged >80 years at baseline were also excluded. The analytical cohort for this study therefore consisted of 98352 women from six countries, 40429 of whom were premenopausal and 57923 of whom were naturally postmenopausal.
Incident breast cancer cases were identified through population cancer registries (Denmark, Italy, Sweden, United Kingdom) or by active follow-up (Germany, Greece), depending on the follow-up systems in each of the participating countries. The active follow-up procedure used a combination of methods including health insurance records, cancer and pathology registries, and via contact with participants and their next-of-kin. Women were followed from study entry (1992–2000) until first breast cancer diagnosis, death, emigration, or end of the follow-up period. By April 2004, 5984 breast cancer cases (invasive n=5386; in situ n=593; unspecified n=4; metastatic n=1) had been reported to the common database at the International Agency for Research on Cancer (IARC), Lyon, based on information on complete follow-up data up till December 2001 or December 2002 in most of the centres. Mortality data were coded according to the 10th Revision of the International Statistical Classification of Diseases, Injuries and Causes of Death (ICD-10), and cancer incidence data were coded according to ICD-O-2. This analysis included 1358 invasive (primary, malignant) breast cancer cases, of which 264 occurred in women who were premenopausal at recruitment and 1094 in postmenopausal women.
Data on recalled weight at age 20 were available for cohorts in Italy (Varese), United Kingdom, Greece, Sweden (Malmö) and Denmark, and for the age of 25 years in Germany (Potsdam). Weight and height at recruitment were measured to the nearest 0.1kg and 0.1 or 0.5cm, respectively, with subjects wearing no shoes.
For the present study, baseline weight was adjusted to reduce heterogeneity due to protocol differences in clothing worn during measurement (Haftenberger et al, 2002). For the ‘health conscious group' in Oxford (UK), linear regression models were used to predict sex- and age-specific values from women from the Oxford general population group with both measured and self-reported body measures (Haftenberger et al, 2002; Spencer et al, 2002). Body mass index was calculated as weight in kg divided by height in meters squared (kgm−2). Subjects with a BMI of 25.0 to <30.0kgm−2 were classified as overweight and those with a BMI of 30.0kgm−2 were classified as obese (World Health Organization, 1998). Adult weight change was calculated as the difference between measured baseline weight at enrolment and recalled weight at age 20 or 25 years.
Information on reproductive, sociodemographic, and lifestyle characteristics was obtained from the standardised health questionnaire at study entry. Other known risk factors included in this analysis were: age at menarche (11, 12, 13, 14, >15 years), age at first pregnancy (first birth <20, 20–30, >30 years, nulliparous), education (none/primary school, technical/professional school, secondary school, university), smoking status (never, former, current), alcohol consumption as ethanol in gday−1 (abstainers, 1–14, 15–30, >30g), leisure physical activity (continuous score), height (continuous), current OC use (no/yes), and current hormone use (no/yes). Current hormone use refers to the use of menopausal hormones at the time of recruitment as derived from the country-specific questionnaires or during interviews, and includes oestrogen alone and combined oestrogen/progestin preparations (referred to as HRT use).
Cox proportional hazards models were used to estimate adjusted hazard ratios (HR) and 95% confidence intervals (CI) of breast cancer incidence for each weight change category. Weight changes were defined as follows: −2 and +2kg as the referent category (stable weight); more than −2kg as weight loss; and more than +2kg as weight gain. The latter was further divided into five weight gain categories (2.1–5.0, 5.1–10.0, 10.1–15.0, 15.1–20.0, >20kg). Age was used as the underlying (primary dependent) time variable in the counting process formulation, with entry time t0 defined as the subject's age at recruitment, and exit time t1 defined as the subject's age at breast cancer diagnosis or censoring date. All multivariate models were stratified (option ‘strata' in SAS-PHREG procedure) by age at recruitment and by study centre to be less sensitive against violations of the proportional hazards assumption, and simultaneously adjusted for the following established or potential breast cancer risk factors: weight at age 20, height, leisure physical activity (as continuous variables), age at menarche, parity, age at first birth, education, smoking status, alcohol consumption, current OC use and current HRT use. An indicator category for missing responses for each covariate was created to minimise the loss of observations due to missing covariate data.
Trend tests were calculated on the basis of category-based scores, assigning a score from 1 to 7 to an individual according to the weight change categories. For country-specific analyses, weight change was treated as categorical and continuous variable. Potential effect modifications of the weight change–breast cancer association were examined by (a) BMI at age 20 (dichotomised at the median BMI for premenopausal women </>21.1kgm−2, and for postmenopausal women 21.3kgm−2) and (b) current HRT use (yes/no in postmenopausal women only). To test for interaction, we used a metric score with median weight change within categories of weight change as the exposure variable. All tests of statistical significance were two-sided and P-values of <0.05 were considered statistically significant. The statistical analyses were performed with the use of the PHREG procedure in the Statistical Analysis System (SAS) software package, version 9 (SAS Institute, Cary, NC, USA).
In total, 98352 European women aged 20–80 years at baseline were followed for an average of 5.8 (±1.6) years and accrued a total of 573102 person years. The median age at diagnosis was 49.0 years for premenopausal and 63.0 years for postmenopausal women. Baseline characteristics are presented in Table 1. Among premenopausal women, the median age at baseline varied substantially across countries due to differences in enrolment protocols between the EPIC centres. Details of other potential risk factors across weight change categories are shown in Table 2. Women with a stable weight between age 20 and study enrolment were more likely to be nulliparous, current smokers, have a university degree, and have had a higher body weight at age 20 than women who gained weight during adulthood (Table 2). On average, 26.6% of postmenopausal women used HRT at baseline. The proportion of both HRT users and OC users was smallest among women with large weight gain. The percentage of smokers was highest among women who lost weight over adulthood (<−2kg).
Table 3 shows the mean weight at age 20 years, adult weight change, weight, and BMI at enrolment in each of the participating countries. Weight was recalled for age 20 in all cohorts except Potsdam (Germany), where weight was recalled at age 25. Premenopausal women from the UK were the heaviest at age 20, and Italian women were the lightest. Subsequent adult weight gain was smallest for the UK women and highest for the Danish women (4.2 vs 12.1kg). This large difference can be in part attributed to the different enrolment age. In all, 22% of premenopausal women had lost weight between age 20 (25) and baseline examination. The mean (s.d.) weight gain for the remaining women was 9.0±8.3kg. At age 20, the prevalence of overweight (BMI 25–30) was 8.2% and the prevalence of obesity (BMI 30) was 1.6%. At age of enrolment, these prevalences had increased to 21.0 and 8.9%, respectively.
Among premenopausal women, long-term weight gain was not associated with breast cancer risk, irrespective of adjustment for potential risk factors (Table 4). Weight loss of more than 2kg was associated with a nonsignificant increased risk of about 50% in each of the tested models. However, this may be due to the effect of pre-existing disease, as, after excluding breast cancer cases diagnosed during the first year of follow-up, the multivariate adjusted risk estimate for weight loss approached unity (HR for <−2kg: 1.01, CI 0.59–1.76 based on 175 cases), while relative risks in the weight gain categories were not materially changed (data not shown).
Initial weight or BMI at age 20 was inversely, but nonsignificantly associated with risk of breast cancer after adjustment for relevant covariates (data not shown), and there was no evidence of statistical interaction between BMI at age 20 and weight change in relation to breast cancer risk.
Similar to premenopausal women, for postmenopausal women, the heaviest women at age 20 were from the UK and the lightest were from Italy (Table 3). On average, postmenopausal women had a weight gain of 11.0kg during adulthood, being smallest for the UK women (8.6kg) and highest for Greek women (15.7kg). In all, 13% of postmenopausal women had lost weight between age 20 and age at study entry. The mean (s.d.) weight gain for the remaining women was 13.5±9.5kg. Hormone replacement therapy users had a smaller mean change in weight than those not taking hormones (10.0±9.4 and 11.7±11.4kg, respectively). At age 20, the proportion of women who were overweight and obese was very similar to that of premenopausal women, although at the age of enrolment the prevalence of overweight (35.2%) and obesity (16.5%) in postmenopausal women was much higher than that of premenopausal women.
Among postmenopausal women overall, there was a positive trend between adult weight gain and breast cancer risk in all of the tested models, although none of the individual categorical risk estimates reached statistical significance (multivariate adjusted HR by weight change category: 0.75 (CI 0.54, 1.04); 1.0 (reference); 0.98 (CI 0.74, 1.29); 1.01 (CI 0.80, 1.28); 1.00 (CI 0.78, 1.27); 1.12 (CI 0.87, 1.45); 1.22 (CI 0.96, 1.56); trend P=0.002). Only after stratification by current HRT use, stronger positive associations between weight gain and breast cancer became apparent among women not currently using HRT at recruitment, and the interaction term between HRT use and weight change approached statistical significance (P=0.10) (Table 5). Compared to women in the reference group (±2kg), women in the upper two categories of weight gain between 15–20kg and >20kg had excess risks of 50 and 52%, respectively, after adjusting for multiple covariates. Among current HRT users, weight gain was not significantly associated with breast cancer risk. Further adjustment for age at menopause (data were available for 87% of the subjects) did not substantially alter the results in nonusers or HRT users. The omission of the first year of follow-up did not substantially alter these associations (data not shown).
Figure 1 shows the relative risk estimates when comparing each combined weight change–HRT use category with a uniform reference category (non-HRT user with stable weight±2kg). Among nonusers, multivariate adjusted relative risks were increased by 22 and 53% in women gaining 2–15kg and >15kg, respectively, compared with women with stable weight. Overall, HRT users experienced a much higher breast cancer risk compared to non-users, irrespective of their change in weight.
Similar to premenopausal women, initial weight and BMI at age 20 were inversely, but nonsignificantly, associated with risk of postmenopausal breast cancer both before and after adjustment for weight change or other covariates (data not shown). There was no evidence of a significant interaction between BMI at age 20 (</>21.3kgm−2) and weight change in relation to breast cancer risk irrespective of HRT use.
Figure 2 shows the multivariate adjusted risk estimates for breast cancer in relation to continuous weight change by 5kg for all cohorts combined and for individual countries with at least 30 cases of breast cancer, stratified by menopausal status and HRT use. Similar to the categorical analyses, there was no association between weight change and breast cancer in premenopausal women or among postmenopausal women using HRT. Among postmenopausal women not using HRT, for one increment of weight change (5kg), the pooled HR was 1.08 (CI 1.04–1.12), with a P-value for linear trend of <0.0001. No evidence of heterogeneity between countries was present for any of the presented analyses.
In this large cohort of women from six European countries, aged 20–80 years at study enrolment, increased weight gain was significantly associated with excess breast cancer risk in postmenopausal, but not in premenopausal, women, independent of other potential risk factors.
Our finding of a nonsignificant inverse association between weight gain and premenopausal breast cancer risk is in line with evidence from the few studies that have examined this (Le Marchand et al, 1988; Brinton and Swanson, 1992; Huang et al, 1997; Coates et al, 1999; Peacock et al, 1999; Friedenreich et al, 2002; Weiderpass et al, 2004). Most of these studies report a risk reduction of about 30% for women in the highest weight change or BMI change category compared to women in the reference group with low weight gain or stable weight. However, in contrast to previous studies (Friedenreich et al, 2002; Weiderpass et al, 2004), weight loss since age 20 was not significantly associated with excess risk in the present study, specifically after excluding the first year of follow-up, which suggests that this association found in other studies may have been a reflection of pre-existing disease.
The biological mechanisms linking adiposity to premenopausal breast cancer risk are not fully understood. There is some evidence that overweight premenopausal women have more irregular and anovulatory menstrual cycles, and hence less cumulative exposure to oestrogen and progesterone, which reduces breast cancer risk (Stoll, 1997; IARC working group, 2002). Notably, the exclusion of women with reported irregular menses and/or infertility did not affect the association between adult BMI and premenopausal breast cancer risk in a Scandinavian cohort (Weiderpass et al, 2004), and low luteal phase serum progesterone levels were associated with higher, and not lower, breast cancer risk in an Italian cohort (Micheli et al, 2004). Further clarification is needed with regard to the underlying mechanisms of the inverse body size–breast cancer association before the menopause.
In postmenopausal women, the weight change–breast cancer association varied by HRT use. The examination of the modifying effect of HRT on the weight change–breast cancer association using a common reference group indicated that the increase in risk by weight gain was clearly evident in women not using HRT. Among current HRT users who have a much higher risk of developing breast cancer, there was no association between adult weight gain and cancer risk.
The effect of HRT use on the association between weight change and breast cancer risk has been previously reported (Huang et al, 1997; Friedenreich et al, 2002; Morimoto et al, 2002; Feigelson et al, 2004). The relative risk estimates in the current analysis are lower than those found in the Nurses' Health Study among women who never used hormones (Huang et al, 1997), but similar to those observed in the Cancer Prevention Study (CPS)-II Nutrition cohort for comparable weight categories (Feigelson et al, 2004). The pooled estimates in the present study indicate that the risk per 5kg weight gained among women not using exogenous hormones increased by 8%, which is in line with a report from a Swedish case–control study, where the excess risk per 5kg was 7% among non-users of HRT (Magnusson et al, 1998).
Our finding lends support to the hypothesis that adiposity increases breast cancer risk through its oestrogenic effects (Key et al, 2001). Weight gain during adult life mainly reflects the deposition of fat mass rather than lean body mass. After menopause, adipose tissue is the major location for the synthesis of oestrogens from androgenic precursors (Siiteri, 1987; Bray, 2002). Accordingly, the increased risk of breast cancer in postmenopausal women who gain large amounts of weight or are overweight is attributed to excess plasma levels of oestrogens, together with low levels of sex-hormone-binding globulin (SHBG) (Stoll, 1994; Thomas et al, 1997; Endogenous Hormones and Breast Cancer Collaborative Group, 2003; Calle and Kaaks, 2004). Use of HRT can obscure the effect of adiposity on breast cancer risk by influencing circulating oestrogen levels; therefore, stratified analyses have been applied in recent studies. The present study found that weight change was not associated with breast cancer risk among current HRT users, which is consistent with previous studies (Harris et al, 1992; Huang et al, 1997; Magnusson et al, 1998; Morimoto et al, 2002; Feigelson et al, 2004) and may be attributable to the higher oestrogen levels from hormone therapy than those derived from adipose tissue (Hankinson et al, 1998; Trentham-Dietz et al, 2000). Whether the small risk reduction observed with increasing weight gain among HRT users in our study is real or due to chance finding remains to be explored in future studies.
It has been proposed that a high BMI in early adult life may influence cancer risk in later life and the potential effect modification by early body size on the association between weight change and breast cancer risk has been previously investigated (Barnes-Josiah et al, 1995; van der Brandt et al, 1997). In the present analysis, body weight at age 20 did not modify the weight change–breast cancer association in postmenopausal hormone users or non-users, which is consistent with the CPS-II Study (Feigelson et al, 2004).
Some limitations of these data should be noted. Our conclusions are based on results derived from a large cohort (cases n=1358), but with a limited follow-up period (5.8 years). Re-examination of our data after the removal of pre-existing disease by excluding individuals diagnosed during the first year of follow-up did not materially change the main findings, but did attenuate the association between weight loss and breast cancer risk among premenopausal women. Extended follow-up will allow us to evaluate the effect of excluding likely pre-existing disease with more confidence. Furthermore, it cannot be ruled out that some confounding bias is still present, due to the lack of inclusion of other unknown potential risk factors.
We were unable to evaluate in more detail the effect of weight gain at different ages, other than that of weight at age 20 and weight at enrolment. To date, only a few studies have been able to disentangle the effects of weight at different ages vs weight gain over a lifetime, indicating no differential effect on breast cancer risk (Trentham-Dietz et al, 1997; Morimoto et al, 2002; Radimer et al, 2004), or the tendency that weight gained after age 50 confers an increased risk (Friedenreich et al, 2002). A further limitation is that weight at age 20 was based on self-reported recall. However, evidence suggests that past body weight is reported with reasonable accuracy in comparison with measured past weight among elderly (Stevens et al, 1990) and middle-aged adults (Casey et al, 1991), even when recalled up to 30 years later. A major strength of this study is that all body measures assessed at enrolment were directly measured in a standardised way, in contrast to the self-reported data used in the majority of previous studies. Thus, nondifferential misclassification of baseline weight should be minimal.
In conclusion, these results show that large weight gain among postmenopausal women who do not use HRT is associated with an increased risk of breast cancer. Among current HRT users, who overall are at a higher risk of breast cancer than non-HRT users, weight gain is not associated with risk. These data provide further support for the positive association of adiposity with breast cancer among postmenopausal women. As obesity has reached epidemic proportions and is also a modifiable lifestyle factor, avoidance of weight gain throughout life is a salient measure for prevention of breast cancer.
We thank all the participants in EPIC, and Ellen Kohlsdorf and Wolfgang Bernigau (EPIC-Potsdam, Germany) for technical assistance. The work described in the paper was carried out with the financial support of the ‘Europe Against Cancer' Programme of the European Commission (SANCO); Deutsche Krebshilfe; German Cancer Research Center; German Federal Ministry of Education and Research; Danish Cancer Society; Cancer Research UK; Medical Research Council, UK; the Stroke Association, UK; British Heart Foundation; Department of Health, UK; Food Standards Agency, UK; the Wellcome Trust, UK; Greek Ministry of Health; Greek Ministry of Education; Italian Association for Research on Cancer; Italian National Research Council; Swedish Cancer Society; Swedish Scientific Council; Regional Government of Skåne, Sweden.