Faculty Bibliography

Prospective cohort studies on breast cancer risk among premenopausal women and insulin-like growth factor I (IGF-I) concentrations have so far included only few cases, and have shown inconsistent relative risk estimates. We pooled 220 cases of breast cancer diagnosed before age 50, and 434 control subjects, from three prospective studies in New York (USA), Umea (Northern Sweden) and Milan (Italy), and we measured IGF-I and insulin-like growth factor binding protein 3 (IGFBP-3) with common enzyme-linked immunosorbent assays. Overall, IGF-I and IGFBP-3 measurements obtained by the common method showed a positive but not significant relationship with breast cancer risk (odds ratios (ORs) 0.90 [95% confidence intervals (95% CI) 0.50-1.62], 1.63 [0.89-2.97], 1.46 [0.78-2.73] and 1.41 [0.75-2.63] for quintiles of IGF-I, and ORs 0.98 [0.54-1.75], 1.06 [0.59-1.91], 1.04 [0.58-1.87] and 1.77 [0.97-3.24] for quintiles of IGFBP-3). Our results give only moderate support for an association of blood IGF-I with breast cancer risk in young women

Because fruits and vegetables are rich in bioactive compounds with potential cancer-preventive actions, increased consumption may reduce the risk of ovarian cancer. Evidence on the association between fruit and vegetable intake and ovarian cancer risk has not been consistent. We analyzed and pooled the primary data from 12 prospective studies in North America and Europe. Fruit and vegetable intake was measured at baseline in each study using a validated food-frequency questionnaire. To summarize the association between fruit and vegetable intake and ovarian cancer, study-specific relative risks (RR) were estimated using the Cox proportional hazards model, and then combined using a random-effects model. Among 560,441 women, 2,130 cases of invasive epithelial ovarian cancer occurred during a maximum follow-up of 7 to 22 years across studies. Total fruit intake was not associated with ovarian cancer risk-the pooled multivariate RR for the highest versus the lowest quartile of intake was 1.06 [95% confidence interval (95% CI), 0.92-1.21; P value, test for trend = 0.73; P value, test for between-studies heterogeneity = 0.74]. Similarly, results for total vegetable intake indicated no significant association (pooled multivariate RR, 0.90; 95% CI, 0.78-1.04, for the highest versus the lowest quartile; P value, test for trend = 0.06; P value, test for between-studies heterogeneity = 0.31). Intakes of botanically defined fruit and vegetable groups and individual fruits and vegetables were also not associated with ovarian cancer risk. Associations for total fruits and vegetables were similar for different histologic types. These results suggest that fruit and vegetable consumption in adulthood has no important association with the risk of ovarian cancer

Circulating insulin-like growth factor-I (IGF-I) and its major binding protein IGF binding protein-3 (IGFBP-3) have been associated with increased risk of premenopausal breast cancer, although risk estimates varied broadly. An extension of a case-control study (138 cases, 259 matched controls) on IGF-I and breast cancer in premenopausal women nested in the New York University Women's Health Study cohort offered the opportunity to address the hypothesis that such variability may have been the result of variations in the ability of different IGFBP-3 assays to specifically measure intact/functional forms of the protein. IGF-I and IGFBP-3 had originally been measured using in-house RIAs. These measurements were repeated using commercially available ELISAs [Diagnostic System Laboratories (DSL), Webster, Texas], and a third ELISA with greater specificity for active forms for IGFBP-3. Pearson's correlations between IGF-I concentrations in the original study and DSL ELISA were very high [r = 0.92; 95% CI, 0.90-0.94]. Correlations with DSL ELISA were much lower for IGFBP-3 (r = 0.58; 0.49-0.66) and even lower still with the assay for functional IGFBP-3 (r = 0.33; 0.20-0.44). IGF-I and IGFBP-3 measurements by the DSL ELISA methods showed statistically significant relationships with risk. The odds ratios (OR) for top versus bottom quartiles were 1.93 (1.00-3.72; P = 0.02) and 2.03 (1.09-3.76; P = 0.02), respectively, in agreement with the original observations. In contrast, measurements of functional IGFBP-3 tended to be unrelated to risk [ORs for the top versus bottom quartile, 0.97 (0.44-2.11)]. The association with IGF-I became substantially weaker and lost statistical significance after adjustment for IGFBP-3 using DSL ELISA, but became considerably stronger when adjusting for the functional IGFBP-3 measurements [OR = 2.43 (1.21-4.90); P = 0.005], or when considering the molar ratio of IGF-I to IGFBP-3 [OR = 2.37 (1.13-5.00); P = 0.02]. These results are consistent with an association of breast cancer risk in young women with elevated IGF-I and IGFBP-3, and show that for IGFBP-3, the strength of such an association could vary substantially depending on the assay used

We assessed the association of sex hormone levels with breast cancer risk in a case-control study nested within the cohort of 7054 New York University (NYU) Women's Health Study participants who were postmenopausal at entry. The study includes 297 cases diagnosed between 6 months and 12.7 years after enrollment and 563 controls. Multivariate odds ratios (ORs) (95% confidence interval (CI)) for breast cancer for the highest quintile of each hormone and sex-hormone binding globulin (SHBG) relative to the lowest were as follows: 2.49 (1.47-4.21), P(trend)=0.003 for oestradiol; 3.24 (1.87-5.58), P(trend)<0.001 for oestrone; 2.37 (1.39-4.04), P(trend)=0.002 for testosterone; 2.07 (1.28-3.33), P(trend)<0.001 for androstenedione; 1.74 (1.05-2.89), P(trend)<0.001 for dehydroepiandrosterone sulphate (DHEAS); and 0.51 (0.31-0.82), P(trend)<0.001 for SHBG. Analyses limited to the 191 cases who had donated blood five to 12.7 years prior to diagnosis showed results in the same direction as overall analyses, although the tests for trend did not reach statistical significance for DHEAS and SHBG. The rates of change per year in hormone and SHBG levels, calculated for 95 cases and their matched controls who had given a second blood donation within 5 years of diagnosis, were of small magnitude and overall not different in cases and controls. The association of androgens with risk did not persist after adjustment for oestrone (1.08, 95% CI=0.92-1.26 for testosterone; 1.15, 95% CI=0.95-1.39 for androstenedione and 1.06, 95% CI=0.90-1.26 for DHEAS), the oestrogen most strongly associated with risk in our study. Our results support the hypothesis that the associations of circulating oestrogens with breast cancer risk are more likely due to an effect of circulating hormones on the development of cancer than to elevations induced by the tumour. They also suggest that the contribution of androgens to risk is largely through their role as substrates for oestrogen production

Mathematical methods exist to determine the fractions of sex hormones bound to albumin, bound to sex hormone binding globulin (SHBG), or unbound, using total hormone concentration and SHBG concentration. We used data from eight prospective studies of postmenopausal women to assess the validity of these estimates for fractions of estradiol (E2) and to investigate the impact of using calculated values in breast cancer relative risk (RR) models. Comparisons were made between measured and calculated concentrations of free and non-SHBG-bound E2 in four studies. Relationships between the hormone fractions were investigated and a sensitivity analysis of the calculation performed. Breast cancer RRs were estimated using conditional logistic regression by quintiles of free E2. There is a high correlation (r > 0.91) between calculated and measured values of both free and non-SHBG-bound E2. The calculation is highly sensitive to total hormone concentration but is relatively insensitive to SHBG concentration. In studies with both measured and calculated values, the RRs of breast cancer by quintile of free E2 were almost identical for both estimates; using calculated values in all possible studies the RR in the highest compared with the lowest quintile of free E2 was 2.29 (95% confidence interval, 1.65-3.19). The mathematical method used to calculate fractions of E2 is valid, and RR analyses using calculated values produce similar results to those using measured values. This suggests that for epidemiological studies, it is only necessary to measure total E2 concentration and SHBG concentration, with hormone fractions being obtained by calculation, producing savings in cost, time, and serum

BACKGROUND: Obesity is associated with increased breast cancer risk among postmenopausal women. We examined whether this association could be explained by the relationship of body mass index (BMI) with serum sex hormone concentrations. METHODS: We analyzed individual data from eight prospective studies of postmenopausal women. Data on BMI and prediagnostic estradiol levels were available for 624 case subjects and 1669 control subjects; data on the other sex hormones were available for fewer subjects. The relative risks (RRs) with 95% confidence intervals (CIs) of breast cancer associated with increasing BMI were estimated by conditional logistic regression on case-control sets, matched within each study for age and recruitment date, and adjusted for parity. All statistical tests were two-sided. RESULTS: Breast cancer risk increased with increasing BMI (P(trend) =.002), and this increase in RR was substantially reduced by adjustment for serum estrogen concentrations. Adjusting for free estradiol reduced the RR for breast cancer associated with a 5 kg/m2 increase in BMI from 1.19 (95% CI = 1.05 to 1.34) to 1.02 (95% CI = 0.89 to 1.17). The increased risk was also substantially reduced after adjusting for other estrogens (total estradiol, non-sex hormone-binding globulin-bound estradiol, estrone, and estrone sulfate), and moderately reduced after adjusting for sex hormone-binding globulin, whereas adjustment for the androgens (androstenedione, dehydroepiandrosterone, dehydroepiandrosterone sulfate, and testosterone) had little effect on the excess risk. CONCLUSION: The results are compatible with the hypothesis that the increase in breast cancer risk with increasing BMI among postmenopausal women is largely the result of the associated increase in estrogens, particularly bioavailable estradiol

BACKGROUND: Follicle-stimulating hormone (FSH), a member of gonadotropin family, is critical for follicular maturation and ovarian steroidogenesis. Serum FSH levels are known to fluctuate during different phases of menstrual cycle in premenopausal women, and increase considerably after the menopause as a result of ovarian function cessation. There is little existing evidence to guide researchers in estimating the reliability of serum FSH measurements. The objective of this study was to assess the reliability of FSH measurement using stored sera from an ongoing prospective cohort - the NYU Women's Health Study. METHODS: Sixty healthy women (16 premenopausal, 44 postmenopausal), who donated at least two blood samples at approximately 1-year intervals were studied. An immunoradiometric assay using a sandwich monoclonal antibodies technique was used to measure FSH levels in serum. RESULTS: The reliability of a single log-transformed FSH measurement, as determined by the intraclass correlation coefficient, was 0.70 for postmenopausal women (95% confidence interval (CI), 0.55-0.82) and 0.09 for premenopausal women (95% CI, 0-0.54). CONCLUSIONS: These results suggest that a single measurement is sufficient to characterize the serum FSH level in postmenopausal women and could be a useful tool in epidemiological research. For premenopausal women, however, the reliability coefficient was low, suggesting that a single determination is insufficient to reliably estimate a woman's true average serum FSH level and repeated measurements are desirable

Experimental and epidemiological evidence supports a role for sex steroid hormones in the pathogenesis of ovarian cancer. We investigated the association between ovarian cancer risk and pre-diagnostic blood concentrations of testosterone, androstenedione, DHEAS, estrone and SHBG. A case-control study nested within 3 cohorts, in New York (USA), Umea (Sweden) and Milan (Italy), included 132 subjects with primary invasive epithelial ovarian cancer. For each case subject, 2 controls were selected who matched a case on cohort, menopausal status, age and date of recruitment and, if premenopausal, day of the menstrual cycle at blood donation. Only women who did not use exogenous hormones at blood donation were included in the study. Conditional logistic regression was used to relate cancer risk to sex steroid hormone concentrations with adjustment for potential confounders. No clear association was observed between ovarian cancer risk and any of the 5 hormones under study. In the premenopausal group, the risk appeared to increase with increasing blood concentrations of androstenedione (upper vs. lower tertile OR = 2.35; 95% CI = 0.81-6.82.), but the small number of subjects in the sub-group precluded reaching unambiguous conclusions about such association. Our study does not support previous observations relating elevations in blood levels of the major sex steroid hormones to an increased risk of ovarian cancer, but offers some evidence that elevated circulating androstenedione before menopause may be associated with increased ovarian cancer risk