Uterine sarcomas are characterised by early age at diagnosis, poor prognosis, and higher incidence among Black compared with White women, but their aetiology is poorly understood. Therefore, we performed a pooled analysis of data collected in the Epidemiology of Endometrial Cancer Consortium. We also examined risk factor associations for malignant mixed mullerian tumours (MMMTs) and endometrioid endometrial carcinomas (EECs) for comparison purposes.
We pooled data on 229 uterine sarcomas, 244 MMMTs, 7623 EEC cases, and 28 829 controls. Odds ratios (ORs) and 95% confidence intervals (CIs) for risk factors associated with uterine sarcoma, MMMT, and EEC were estimated with polytomous logistic regression. We also examined associations between epidemiological factors and histological subtypes of uterine sarcoma.
Significant risk factors for uterine sarcoma included obesity (body mass index (BMI)⩾30 vs BMI<25 kg m−2 (OR: 1.73, 95% CI: 1.22–2.46), P-trend=0.008) and history of diabetes (OR: 2.33, 95% CI: 1.41–3.83). Older age at menarche was inversely associated with uterine sarcoma risk (⩾15 years vs <11 years (OR: 0.70, 95% CI: 0.34–1.44), P-trend: 0.04). BMI was significantly, but less strongly related to uterine sarcomas compared with EECs (OR: 3.03, 95% CI: 2.82–3.26) or MMMTs (OR: 2.25, 95% CI: 1.60–3.15, P-heterogeneity=0.01).
In the largest aetiological study of uterine sarcomas, associations between menstrual, hormonal, and anthropometric risk factors and uterine sarcoma were similar to those identified for EEC. Further exploration of factors that might explain patterns of age- and race-specific incidence rates for uterine sarcoma are needed.
Uterine sarcoma is a rare form of uterine cancer that arises from the myometrium or connective tissue of the uterus and accounts for 3–7% of all uterine cancer diagnoses in the United States (D'Angelo and Prat, 2010). Unlike the most common uterine cancer histological type, endometrioid endometrial carcinoma (EEC), uterine sarcomas are highly aggressive, with 5-year overall survival rates ranging between 17 and 55% (Prat, 2009). The peak incidence of uterine sarcoma occurs at a younger age than EEC and several studies reported higher incidence rates of uterine sarcoma among Black compared with White women (Harlow et al, 1986; Schwartz et al, 1996; Brooks et al, 2004), the opposite of overall endometrial carcinoma trends (Sherman and Devesa, 2003).
Owing to the low incidence of this disease, the aetiology of uterine sarcomas has been investigated in only a few small case–control studies (Kvale et al, 1988; Schwartz and Thomas, 1989; Schwartz and Weiss, 1990; Schwartz et al, 1991, 1996; Lavie et al, 2008; Jaakkola et al, 2011). Obesity, menopausal use of oestrogen plus progestin, oral contraceptives (OC), and tamoxifen use are associated with increased risks of uterine sarcoma, whereas cigarette smoking and parity are associated with a reduced risk. Recently, there was an important change in the classification of uterine sarcoma; malignant mixed mullerian tumours (MMMTs), which previously accounted for 40% of all uterine sarcomas, are now classified as metaplastic endometrial carcinomas given their similarities in aetiology and metastatic patterns (McCluggage, 2002; Prat, 2009). Consequently, previous risk factor associations may have been affected by the inclusion of the MMMT subtype. Here, we examine relationships between epidemiological risk factors and uterine sarcoma, overall and by histological subtype, in a large pooled analysis using the updated histological classification for uterine sarcoma. Furthermore, we examine risk factor associations for MMMTs and EECs to evaluate potential aetiologic heterogeneity across a spectrum of uterine cancer diagnoses.
Materials and Methods
The Epidemiology of Endometrial Cancer Consortium (E2C2), sponsored in part by the National Cancer Institute, was designed to combine data from cohort and case–control studies to elucidate the aetiology of uterine cancer (Olson et al, 2009). Any study that included at least one uterine sarcoma case was eligible for the current analysis. The 10 cohort and five case–control studies that contributed data to this analysis are summarised in Table 1. For the cohort studies that contributed data to E2C2 (other than the California Teachers Study (CTS)), a nested case–control study design was employed, with inclusion of up to four controls (women with an intact uterus and no uterine cancer diagnosis) randomly selected from the risk set and matched to the corresponding uterine cancer case on year of birth, date of entry (within 6 months), and any additional matching criteria as appropriate in the individual study. For the CTS, data came from a previous nested case–control study in which two controls per case were identified and matching was based on 5-year age group, race/ethnicity, and broad geographic area within California. Cases in the cohort studies were identified through annual linkage to state or national cancer registries (Multiethnic Cohort Study, NIH-AARP Diet and Health Study (NIH-AARP), Iowa Women's Health Study (IWHS), Netherlands Cohort Study (NLCS), Canadian National Breast Screening Study (NBSS), and CTS) or by self-report on follow-up questionnaires and confirmed through medical record review, linkage to cancer registries, or the National Death Index (Cancer Prevention Study II Nutrition Cohort, Breast Cancer Detection Demonstration Project (BCDDP), Nurses’ Health Study (NHS), and Black Women’s Health Study (BWHS)).
In the case–control studies, population-based controls were frequency-matched to cases except in the US Case–Control Study (US) where individual 1 : 1 matching was employed. Eligible controls were those women with an intact uterus and no history of uterine cancer. Methods to select controls within each source population included random digit dialling (US, Bay Area Womens Health Study (BAWHS), Endometrial Cancer and Physical Activity Study (ECPA)) and random selection from data registrars of all citizens (Polish Endometrial Cancer Study (PECS) and Shanghai Endometrial Cancer Study (SECS)). All studies were approved by the institutional review boards (IRBs) of their parent institutions, and written informed consent was obtained from all participants. In addition, Memorial Sloan–Kettering Cancer Centre has IRB approval as the data coordinating centre for E2C2.
De-identified data from the participating studies were centrally collected and harmonised at Memorial Sloan–Kettering Cancer Centre. We made an effort to collect a core set of standardized variables, but not all variables were collected by each study. Some studies did not provide information on menopausal oestrogen plus progestin use (NBSS, ECPA, NLCS, IWHS, BCDDP), menopausal oestrogen-alone use (NBSS, ECPA, IWHS), diabetes (BAWHS and NBSS), parity (NLCS), or smoking status (BAWHS). As the number of live births was not reported by the NLCS, we used the number of pregnancies lasting ⩾7 months as a surrogate for parity among NLCS cases and controls.
Women with an incident, histologically confirmed diagnosis of uterine sarcoma, MMMT, or EEC were included as case patients in the current study. Although the emphasis of this study is on uterine sarcomas, women with MMMTs or EECs were included for comparison purposes. Uterine sarcoma cases with the following International Classification of Diseases for Oncology (ICD)-O-3 morphology codes were included: sarcoma, not otherwise specified (NOS) 8800–8806, fibromatous neoplasms 8810–8815, myomatous neoplasms 8890–8896 (includes leiomyosarcoma), rhabdomyosarcoma 8900–8902, embryonal rhabdomyosarcoma 8910–8912, and endometrial stromal sarcoma 8930–8934. Four studies (PECS, SECS, BWHS, and NHS) did not have ICD-O-3 codes and instead supplied a summary histology variable for each case (i.e., sarcoma, EEC, MMMT, etc). The ICD-O-3 codes 8950–8982 or summary variable ‘MMMT’ were used to define MMMT, while ICD-O-3 codes 8380–8383 and summary variable ‘endometrioid’ identified EECs. EEC cases from the NHS could not be distinguished from adenocarcinoma, NOS cases and were excluded from analysis.
Categories for exposure variables were created including age (⩽54, 55–59, 60–64, 65–69, ⩾70 years), race (White, Black, Asian, other), BMI (<25, 25–30, ⩾30 kg m−2), age at menarche (<11, 11–12, 13–14, ⩾15 years), menopausal status (premenopausal, peri-menopausal, postmenopausal), parity (no live births, 1 or more live births), number of live births among parous women (1, 2, 3–4, ⩾5 live births), smoking status (never, former, current), menopausal hormone use (never, ever), menopausal oestrogen use (never, ever), menopausal oestrogen plus progestin use (never, ever), OC use (never, ever), and history of diabetes (no, yes). Given the importance of these variables in the aetiology of common endometrial carcinoma subtypes, we included all exposure variables simultaneously in an unconditional polytomous logistic regression model to estimate the magnitude of association (odds ratios (ORs) and 95% confidence intervals (CIs)) between risk factors and case groups. Polytomous logistic regression was used when the outcome variable is nominal with more than two levels (Hosmer, 2000). When a study did not report values for a particular variable, that study was excluded from the specific risk factor analysis. Missing values were coded as a separate category for each variable; when excluding subjects with missing values the results did not appreciably change.
All models were adjusted for age and race; however, we do not present effect estimates for these variables given their use as matching criteria in all studies. Tests for linear trend were performed for BMI, age at menarche, and number of live births among parous women by including the ordinal form of each variable in the model. We also examined risk factors for endometrial stromal sarcoma and leiomyosarcoma, the two main histological subtypes of uterine sarcoma, compared with controls. Differences in ORs between case groups were quantified using case-only logistic regression models. A P-heterogeneity <0.05 indicated the magnitude of effect for a particular risk factor was significantly different between case groups. Between-study heterogeneity of effect estimates was examined by creating a multiplicative interaction term between study site (fixed effect covariate) and each risk factor and performing a likelihood ratio test comparing models with and without the risk factor-study site interaction terms.
Using the distribution of risk factors in our sample, a binary outcome (control vs uterine sarcoma), power of 80% and a two-sided α of 0.05, we calculated minimum detectable ORs for each risk factor, which ranged from 1.45–1.89 for factors associated with increased risk and 0.35–0.67 for protective factors. All tests of statistical significance were two-sided. Analyses were performed using SAS version 9.3 (SAS Institute Inc., Cary, NC, USA).
A total of 229 uterine sarcomas, 244 MMMTs, 7623 EECs, and 28 829 controls were available for this pooled analysis. Black race was more prevalent among MMMTs compared with uterine sarcoma and EEC cases (17.2%, 11.3%, and 2.6%, respectively, data not tabled), and median age at diagnosis was oldest among MMMT cases compared with uterine sarcoma and EEC cases (67.0, 61.4, and 64.3 years, respectively, data not tabled). Distributions of risk factors, ORs, and 95% CIs are shown in Table 2. Significantly increased risk of uterine sarcoma was observed for obese compared to normal BMI (OR: 1.73, 95% CI: 1.22–2.46) and a history of diabetes compared with no diabetes (OR: 2.33, 95% CI: 1.41–3.83), whereas older age at menarche (age at menarche ⩾15 compared with age at menarche <11 years OR: 0.70, 95% CI: 0.34–1.44, p-trend=0.04) was associated with a lower risk of uterine sarcoma. Any live births, postmenopausal status, OC use, and current or former smoking were inversely but not statistically significantly associated with uterine sarcoma risk. BMI was significantly, but less strongly related to uterine sarcoma than to EECs (OR: 3.03, 95% CI: 2.82–3.26) or MMMTs (OR: 2.25, 95% CI: 1.60–3.15) for the heaviest compared with the leanest women (P-heterogeneity=0.01).
In exploratory analyses, we examined risks associated with the most prevalent histological subtypes of uterine sarcoma: endometrial stromal sarcoma (n=98) and leiomyosarcoma (n=82) (Table 3). Black race was more prevalent among leiomyosarcoma compared with endometrial stromal sarcoma cases (20.7% vs 6.1%, data not tabled), whereas median age at diagnosis was similar (61.8 and 63.6 years, respectively, data not tabled). The direction of most associations for the histological subtypes was similar to patterns observed for uterine sarcoma overall. Obesity (OR: 1.74, 95% CI: 1.03–2.93) and a history of diabetes (OR: 2.28, 95% CI: 1.02–5.12) were associated with significantly higher risks of endometrial stromal sarcoma, whereas reduced risk of leiomyosarcoma was observed for postmenopausal compared with premenopausal women (OR: 0.35, 95% CI: 0.16–0.75). Compared with the overall associations, less consistency in histological subtype associations was noted for age at menarche and former or current smoking. However, no significant heterogeneity of effects between these two histological subtypes was observed (P-heterogeneity >0.10).
The present pooled analysis examined the association between previously identified endometrial carcinoma risk factors—including reproductive, hormonal, and anthropometric factors—and uterine sarcoma, a rare yet fatal uterine cancer subtype. Our data suggest that uterine sarcoma shares certain risk factors with EECs but less so with MMMTs. Similar to EEC, obesity and history of diabetes were linked with an increased risk of uterine sarcoma, while older age at menarche was associated with decreased risk. Subtype analyses of endometrial stromal sarcoma and leiomyosarcoma generally revealed risk factor associations similar to those observed for all uterine sarcomas combined.
Uterine sarcomas fall under the broad category of soft tissue sarcomas, which are extremely rare regardless of the site of origin. Previously documented risk factors for this heterogeneous group of tumours include ionising radiation, exposure to certain chemicals, and genetic syndromes, such as neurofibromatosis type 1 and Li-Fraumeni syndrome (Skubitz and D'Adamo, 2007). Uterine sarcomas have been particularly difficult to examine owing to changes in classification over time, histological diversity, and low incidence rates. In 2009, the International Federation of Gynaecology and Obstetrics reclassified MMMTs, which at the time was the most common uterine sarcoma histology subtype (40%), as a metaplastic endometrial carcinoma. Moreover, the remaining uterine sarcoma subtypes—leiomyosarcoma, endometrial stromal sarcoma, adenosarcoma, and undifferentiated sarcoma—are a heterogeneous group, which complicates the study of their aetiology. The two most common subtypes now, leiomyosarcoma and endometrial stromal sarcoma, can be distinguished by their sarcomatous appearance during histology examination. However, expert pathologists are needed for the correct classification of these subtypes (Chu et al, 2001).
Our results support findings from some previous studies on risk factors for specific histological subtypes of uterine sarcoma. In a case–control study (167 cases, 208 controls), Schwartz et al (1991, 1996) reported on uterine sarcoma subtype risks associated with exogenous hormone use, obesity, smoking, and menstrual and reproductive characteristics. As in our study, high BMI was associated with increased risks of endometrial stromal sarcoma (n=26), while the risk of leiomyosarcoma (n=56) was lower among cigarette smokers than never smokers. Although we observed inverse associations with current smoking status for uterine sarcoma overall (OR: 0.88) and for leiomyosarcoma (OR: 0.75), these associations did not achieve statistical significance. Prior reports also suggest decreased uterine sarcoma risk associated with older age at menarche (Kvale et al, 1988; Schwartz et al, 1991), which was apparent in our study for uterine sarcoma risk overall and of the endometrial stromal sarcoma subtype. Parity was associated with decreased uterine sarcoma risk in a prior study (Kvale et al, 1988); however, our results concur with two other reports that did not observe clear associations with any live births, the number of live births, and uterine sarcoma risk (Schwartz and Thomas, 1989; Schwartz et al, 1991).
In contrast to prior reports, we observed statistically non-significant inverse associations between OC use and uterine sarcoma risk overall, as well as risk of both histological subtypes, whereas Schwartz et al. (1996) reported positive, albeit, statistically non-significant associations. Given the absence of statistical significance and information on the formulation and duration of OC use in ours and the previous study, these findings should be interpreted cautiously. Furthermore, we did not observe an association between menopausal oestrogen plus progestin use and uterine sarcoma risk, which has been observed previously. In a recent Finnish cohort study, menopausal estradiol and progestin treatment was associated with increased risks of leiomyosarcoma and endometrial stromal sarcoma, especially among women with longer exposures (Jaakkola et al, 2011). Finally, the relationship between a history of diabetes and uterine sarcoma risk has been explored in one previous study (Brinton et al, 2005). Of 137 uterine sarcoma cases, only 2 had a history of diabetes resulting in a null association. We noted strong risks associated with a history of diabetes for uterine sarcoma overall and both histological subtypes, which is consistent with aetiologic studies of endometrial carcinoma (Weiderpass et al, 2000; Rosato et al, 2011). Obesity and diabetes are associated with metabolic disturbances and our finding of a stronger association with diabetes for uterine sarcoma compared with EEC raises questions about the possibility of a more central role of insulin in their aetiology.
Similarities in risk factor associations for uterine sarcoma and EECs suggest overlap in the biological mechanisms associated with development of these tumours. Commonly described mechanisms relating menstrual, reproductive, and anthropometric factors to EEC risk include imbalances in multiple pathways, including sex hormones (oestrogen and progesterone), insulin and insulin-like growth factors (IGFs), and inflammatory markers such as interleukins. Higher expression of oestrogen, IGFs, and interleukins is associated with increased risk of EECs (Calle and Kaaks, 2004; Oh et al, 2004; Dossus et al, 2010; Audet-Walsh et al, 2011; Wang et al, 2011). Key cytogenetic and molecular events observed in endometrial stromal sarcomas include chromosomal rearrangements, loss of heterozygosity of tumour suppressor genes, and deregulation of the Wnt signalling pathway (Chiang and Oliva, 2011), while leiomyosarcomas are characterised by chromosome 1 deletion. The relationship between aetiologic risk factors and these molecular data is lacking, but this information would allow for a better understanding of uterine sarcoma tumour biology.
Our pooled analysis has several strengths, including the largest sample size of uterine sarcomas examined in the literature to date and availability of data on important risk factors and confounders. Several limitations of the current analysis should be noted. Although our sample size was large relative to previous studies, the histological subtype analyses were affected by small numbers as evidenced by large CIs. The ascertainment of exposure variables differed across studies, potentially introducing misclassification bias. Because of these differences, some variables were classified using crude categories to harmonise across studies. Importantly, we did not observe between-study statistical heterogeneity for any variable under consideration. We had insufficient data from the studies in the pooled analysis on other risk factors of interest, including infertility history, tamoxifen use, history of uterine fibroids, and previous cancer diagnoses. Other novel risk factors, including occupational exposures (Koivisto-Korander et al, 2012) and in vitro fertilisation (Venn et al, 2001), have been examined infrequently and should be studied in appropriate epidemiological settings. Disease misclassification is another possible bias given the potential for differential diagnosis of uterine cancer across diagnosis years, regions, and countries represented by the individual studies. Although MMMTs have recently been excluded from the uterine sarcoma classification, we expect a small proportion of these tumours to be misclassified as primary uterine sarcomas. Finally, this pooled analysis included cases and controls from diverse geographic regions, potentially introducing clinical heterogeneity in our study design. In conclusion, we provide evidence of common aetiologic pathways for EEC and uterine sarcoma. Further exploration of factors that might explain patterns of age- and race-specific incidence rates for uterine sarcoma are needed.
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This research was supported by the Intramural Research Program of the National Cancer Institute, National Institutes of Health.
The authors declare no conflict of interest.
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Felix, A., Cook, L., Gaudet, M. et al. The etiology of uterine sarcomas: a pooled analysis of the epidemiology of endometrial cancer consortium. Br J Cancer 108, 727–734 (2013). https://doi.org/10.1038/bjc.2013.2
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