Introduction
Breast cancer is the most common cancer for women. Worldwide, 2.4 million new cases of breast cancer and 534,000 deaths from breast cancer occurred in 2015 [1]. It is estimated that breast cancer accounts for 1 in 3 new cancer cases in American women, and over 40,000 American women die from breast cancer in 2018 [2]. Previous epidemiological studies have established many risk factors for breast cancer including first-degree family history of breast cancer, early age at menarche, nulliparity, late age at first birth, late age at menopause, overweight or obesity, breast density, exogenous hormone use, and history of benign breast biopsy [3]. All these factors together explain up to 70% of breast cancer burden among postmenopausal women in the USA [4‐6]. New predictors for breast cancer risk may help identify women at higher risk of breast cancer.
Telomeres are tandemly repeated sequences of TTAGGG located at the distal ends of linear chromosomes [7]. They play an essential role in maintaining the structural integrity of chromosomes and regulating cell replication through preventing DNA double-strand breaks, end-to-end chromosome fusions, and degradation [8]. Owing to the incomplete DNA replication at the end of chromosome, telomeres shorten by 50–200 bp during each cell division [9]. Progressive telomere shortening often leads to genomic instability and eventually results in apoptosis or cellular senescence [10]. This progress is considered as a tumor suppressor mechanism, as it limits the number of cell replication cycles [7]. However, if cells bypass senescence due to dysfunctional checkpoint pathways, the telomeres will continue to shorten, driving chromosome fusion and genomic instability. Survivors of this telomere crisis then maintain telomeres, a cancer hallmark, by upregulating telomerase in most cases [11]. Thus, these surviving cells with longer telomeres have a replicative advantage [12], consequently undergo more cell divisions prior to telomere crisis, resulting in the increased likelihood for acquiring mutations that drive malignant transformation [12].
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In the last decade, a growing number of studies have examined the association between telomere length and the risk of cancer. To date, 8 retrospective case-control studies [13‐20] and 5 prospective studies [20‐24] have been published on the relationship between telomere length and risk of breast cancer where their results have been mixed. Some studies [13, 14] reported a positive while others [15, 19‐21] found a negative association between telomere length and breast cancer. The remaining studies showed a null association [16‐18, 20, 22‐24]. In addition, recent prospective epidemiological studies have shown that longer telomeres are associated with increased risk of several cancer types including lung cancer [25, 26], prostate cancer [27], and pancreatic cancer [28]. However, the data from prospective epidemiological studies on telomere length and the risk of breast cancer are sparse. Utilizing the Singapore Chinese Health Study, a prospective study of more than 60,000 middle-aged or older Chinese men and women in Singapore, we investigated the association between telomere length and the risk of developing breast cancer.
Materials and methods
Study population
The present study was based on the data from the Singapore Chinese Health Study, a population-based prospective cohort study with original aims of investigating the role of diet, environmental exposures, and genetic factors on the etiology of cancer and other chronic diseases among Chinese in Singapore. The Institutional Review Boards of the National University of Singapore and the University of Pittsburgh approved the study. Detailed information on study design and methods has been described elsewhere [29]. Briefly, a trained interviewer administered an in-person interview to each consented participant using a structured questionnaire that solicited information on demographics, body weight and height, lifetime use of tobacco, current physical activity, menstrual and reproductive history (for women only), medical history, and family history of cancer. All baseline interviews to 63,257 participants were completed during 1993–1998.
The first follow-up interview was conducted in 1999–2003 to all surviving cohort participants. A total of 52,326 (90.6%) surviving participants completed the follow-up interview that updated information on cigarette smoking, alcohol drinking, history of respiratory diseases and other medical conditions, medication use, current body weight and height, and current menopausal status (for women).
Blood and urine samples were initially collected from a 3% random sample of cohort participants which began in April 1994. We expanded the biospecimen collection to all surviving cohort participants who consented for blood and urine donation at the end of the first follow-up interview. By the end of 2005, 28,346 (57%) of all eligible participants provided blood specimens. Blood components (plasma, serum, buffy coat, and red blood cells) were then stored at − 80 °C for future analyses.
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The present study included 14,305 women who completed the baseline and first follow-up interviews and donated a blood sample. These women were younger and more educated, otherwise comparable with women who did not provide blood samples (n = 20,998) in terms of body mass index, alcohol consumption, cigarette smoking, age when period became regular, family history of breast cancer, and number of hours slept per day (see Additional file 1: Table S1).
Assessment of breast cancer cases
All incident cancer cases and death among cohort participants were identified by annual record linkage analysis with the databases of the Singapore Cancer Registry and the Birth and Death Registry, respectively [30]. According to the latest record, only 56 (< 0.1%) of the total 63,257 original cohort subjects were unknown to their cancer or vital status due to migration out of Singapore. Breast cancer was defined as the tenth revision of the International Classification of Diseases (ICD) and Related Health Problems codes C50.0–C50.9. As of December 31, 2015, after a mean follow-up period of 12.3 years, 442 women who were free of cancer at the time of blood collection developed breast cancer, which were included in the present analysis.
Laboratory methods (for telomere length measurement)
Genomic DNA was extracted from the buffy coat in the peripheral blood sample using QIAamp 96 DNA Blood Kits (Qiagen, Valencia, CA) according to the manufacturer’s protocol. Relative telomere length was measured by comparing the ratio of telomere repeat number (T) to a single copy gene number for albumin (S) in the experimental sample to a standardized reference sample values using multiplexed quantitative polymerase chain reaction (PCR) method developed by Cawthon [31]. This simple and rapid method allowed us to use smaller amounts of DNA to get a relative telomere length and achieve a large population [32]. The experimental sample and reference sample kept the same relative quantity of a single copy gene and telomere repeats by controlling the number of PCR cycles needed to generate a given number of PCR product. PCR reaction was set up in the 96-well plate in the Bio-Rad MyiQ Single-Color Real-Time PCR Detection System by aliquoting 15 μL master mix and 10 μL of experimental DNA sample into each reaction well. The reference standard DNA curve was made from a pooled sample of 77 participants from the Singapore Chinese Health Study identified in a previous study. The reference samples were serially diluted in 5 concentrations in every 96-well plate to provide a relative quantitation. All experimental samples were assayed in duplicate, and the average value of the 2 replicates was used for the final analysis for each subject. The mean coefficient of variation, as a measure of reproducibility, of all technical sample duplicates for telomere length in the present study was 3.5%.
Statistical analysis
Before the statistical analysis, we reconstructed the variables for BMI, cigarette smoking, alcohol consumption, menopausal status and age at menopause, use of oral contraceptives, and use of hormonal therapy based on both responses by study participants at baseline and follow-up 1 interviews. t test and χ2 test were performed to compare the distributions of the selected variables in continuous and discrete values, respectively, between breast cancer cases and non-cancer cases. Analysis of covariance (ANCOVA) was also used to examine the difference in mean relative telomere lengths by the levels of BMI, smoking status, alcohol consumption, and menstrual and reproductive history in all women after adjusted for age at sample collection and father dialect.
The Cox proportional hazard regression method was used to examine the association between relative telomere length and the risk of breast cancer. Person-years for each study participant at risk were calculated from the date of blood sample collection to the date of breast cancer diagnosis, death, migration out of Singapore, or 31 December 2015, whichever occurred first. Study subjects were grouped into quartile levels of telomere length according to the following interquartile range of relative telomere lengths: 0.73–0.85 (Q1), 0.92–0.99 (Q2), 1.06–1.13 (Q3), and 1.23–1.40 (Q4). The magnitude of the association between telomere length and breast cancer risk was measured by hazard ratios (HRs) and corresponding 95% confidence intervals (95% CIs). Tests for linear trend were carried out by taking quartiles of telomere length as an ordinal variable in the Cox model. The proportional hazard assumption was examined using the Schoenfeld method [33] that did not show any violation to the proportionality assumption.
Two sets of Cox regression models were employed in assessing the association between telomere length and breast cancer risk. The first model included age (years) at blood draw and dialect group (Hokkien or Cantonese) as covariates whereas the second model included additional covariates as follows: level of education (no formal education, primary school, or secondary school and above), BMI (< 23.0 kg/m2 or ≥ 23.0 kg/m2 according to the recommendation by the World Health Organization (WHO) for Asian populations [34]), age at first live birth (< 20, 21–25, 26–30, or ≥ 31 years), number of live births (0, 1–2, 3–4, or ≥ 5), age at menopause (≤ 49, 50–54, or ≥ 55 years), use of hormone therapy (never, ever, or current), use of oral contraceptives (no or yes), family history of breast cancer (no or yes), smoking status (never, former, or current smoker), alcohol consumption (non-drinker, < 7, or ≥ 7 drinks per week), weekly vigorous work or strenuous sports (no or yes), and number of hours of sleep.
Effect modification on the association between telomere length and breast cancer risk was examined for age and BMI based on model 2, which included a product term of the modifier and telomere length. Sensitivity analysis was conducted using the same multivariate Cox regression model (model 2) to examine if the association between telomere length and risk of breast cancer was similar for women with shorter (e.g., < 5 years) and those with longer (e.g., ≥ 5 years) follow-up after blood collection.
All statistical analyses were conducted using SAS 9.4 software package (SAS Institute, Cary, NC). All P values reported are two sided. P < 0.05 was considered statistically significant.
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Results
The present analysis included 442 incident breast cancer cases and 13,863 women who were free of breast cancer (non-cancer cases) at the end of follow-up for the present analysis. Fifty-three percent of women were Hokkiens and 47% were Cantonese. The mean age at breast cancer diagnosis was 61.1 [standard deviation (SD) 7.4]. The median time interval from the date of blood collection to the date of breast cancer diagnosis was 6.3 years (range from < 1 month to 18.4 years).
Table 1 shows the distributions of participants’ characteristics and their association with risk of breast cancer. High levels of BMI and education, early age when menstrual period became regular, late age at first live birth, nulliparous or fewer number of live births, and late age at menopause were statistically significantly or borderline significantly associated with higher risk of breast cancer. Alcohol consumption, cigarette smoking status, weekly vigorous work or strenuous sports, use of oral contraceptives, use of hormonal therapy, number of hours of sleep, or familial history of breast cancer were not significantly associated with risk of breast cancer.
Table 1
Distributions of participants’ characteristics and their corresponding hazard ratio for breast cancer among women, the Singapore Chinese Health Study
Characteristics | Non-cancer cases, N (%) | Breast cancer cases, N (%) | HR1 (95% CI) |
P
1
|
|---|---|---|---|---|
Body mass index§, kg/m2 | ||||
< 18.5 | 992 (7.2) | 24 (5.4) | 1.00 (ref) | 0.002 |
18.5 to < 23.0 | 5700 (41.1) | 159 (36.0) | 1.09 (0.71, 1.68) | |
23.0 to < 27.5 | 5521 (39.8) | 195 (44.1) | 1.43 (0.93, 2.18) | |
≥ 27.5 | 1650 (11.9) | 64 (14.5) | 1.56 (0.97, 2.49) | |
Level of education | ||||
No formal education | 4471 (32.3) | 109 (24.7) | 1.00 (ref) | 0.013 |
Primary school | 5840 (42.1) | 194 (43.9) | 1.24 (0.97, 1.58) | |
Secondary school and above | 3552 (25.6) | 139 (31.5) | 1.42 (1.08, 1.86) | |
Alcohol consumption§ (drinks/week) | ||||
None | 12,403 (89.5) | 385 (87.1) | 1.00 (ref) | 0.15 |
< 7 | 1283 (9.3) | 48 (10.9) | 1.14 (0.84, 1.53) | |
≥ 7 | 177 (1.3) | 9 (2.0) | 1.57 (0.81, 3.05) | |
Physical activity (weekly) | ||||
No | 10,103 (72.9) | 318 (72.0) | 1.00 (ref) | 0.91 |
Yes | 3760 (27.1) | 124 (28.1) | 1.01 (0.82, 1.25) | |
Smoking status§ | ||||
Never | 12,639 (91.2) | 414 (93.7) | 1.00 (ref) | 0.39 |
Former/current | 1224 (8.8) | 28 (6.3) | 0.84 (0.57, 1.24) | |
Age when period became regular§ | ||||
< 13 | 1918 (13.8) | 70 (15.8) | 1.61 (1.09, 2.38) | 0.016 |
13–14 | 4977 (35.9) | 175 (39.6) | 1.61 (1.14, 2.26) | |
15–16 | 4435 (31.9) | 143 (32.4) | 1.53 (1.08, 2.16) | |
≥ 17 | 2045 (14.8) | 42 (9.5) | 1.00 (ref) | |
Never regular | 488 (3.5) | 12 (2.7) | 1.13 (0.59, 2.15) | |
Age at first live birth | ||||
< 20.0 | 2363 (17.1) | 57 (12.9) | 1.00 (ref) | 0.005 |
21.0–25.0 | 5195 (37.5) | 162 (36.7) | 1.19 (0.88, 1.61) | |
26.0–30.0 | 3840 (27.7) | 122 (27.6) | 1.15 (0.84, 1.59) | |
≥ 31 | 1475 (10.6) | 51 (11.5) | 1.27 (0.86, 1.86) | |
Nulliparous | 990 (7.1) | 50 (11.3) | 1.90 (1.29, 2.80) | |
Number of live births | ||||
0 | 977 (7.1) | 50 (11.3) | 1.00 (ref) | 0.0002 |
1–2 | 4213 (30.4) | 159 (36.0) | 0.70 (0.51, 0.97) | |
3–4 | 5591 (40.3) | 157 (35.5) | 0.54 (0.39, 0.74) | |
≥ 5 | 3082 (22.2) | 76 (17.2) | 0.54 (0.37, 0.79) | |
Age at menopause§ | ||||
≤ 49 | 2371 (17.1) | 54 (12.2) | 1.00 (ref) | 0.05 |
50–54 | 3284 (23.7) | 92 (20.8) | 1.21 (0.86, 1.69) | |
≥ 55 | 8208 (59.2) | 296 (67.0) | 1.43 (1.00, 2.05) | |
Family history of breast cancer | ||||
No | 13,631 (98.3) | 434 (98.2) | 1.00 (ref) | 0.96 |
Yes | 232 (1.7) | 8 (1.8) | 1.02 (0.51, 2.05) | |
Use of hormone therapy§ | ||||
Never | 11,543 (83.3) | 347 (78.5) | 1.00 (ref) | 0.10 |
Ever | 1540 (11.1) | 62 (14.0) | 1.26 (0.96, 1.65) | |
Current | 780 (5.6) | 33 (7.5) | 1.21 (0.84, 1.74) | |
Use of oral contraceptive | ||||
Never | 9586 (69.2) | 302 (68.3) | 1.00 (ref) | 0.70 |
Former/current | 4277 (30.9) | 140 (31.7) | 0.98 (0.78, 1.18) | |
Sleeping hours | ||||
≤ 6 h | 4737 (34.2) | 134 (30.3) | 0.84 (0.69, 1.04) | 0.48 |
7–8 h | 8218 (59.3) | 285 (64.5) | 1.00 (ref) | |
≥ 8 h | 908 (6.6) | 23 (5.2) | 0.75 (0.49, 1.15) | |
The mean relative telomere lengths by observed or potential risk factors for breast cancer are shown in Table 2. As reported previously [26], age was inversely correlated with telomere length (r = − 0.24; P ≤ 0.0001) and accounted for 5.5% of the telomere length variation (P < 0.0001). After adjustment for age and father dialect as the cohort recruitment criteria factors, a greater number of live births, postmenopausal status, Hokkien dialect, and shorter duration of sleep were significantly or borderline significantly associated with longer telomeres.
Table 2
Mean relative telomere length by characteristics of women, the Singapore Chinese Health Study
Variables | Age at blood draw | Number | Telomere length (95% CI) |
P
1
|
|---|---|---|---|---|
Age at sample collection, years | ||||
45 to < 55 | 52.5 | 2452 | 1.11 (1.10, 1.12) | < 0.0001 |
55 to < 60 | 56.8 | 3528 | 1.09 (1.08, 1.09) | |
60 to < 65 | 62.0 | 3173 | 1.04 (1.03, 1.05) | |
≥ 65 | 70.9 | 5152 | 0.98 (0.97, 0.99) | |
Body mass index, kg/m2 | ||||
< 18.5 | 63.6 | 1016 | 1.04 (1.02, 1.05) | 0.21 |
18.5 to < 23.0 | 61.8 | 5859 | 1.05 (1.04, 1.05) | |
23.0 to < 27.5 | 62.6 | 5716 | 1.05 (1.04, 1.05) | |
≥ 27.5 | 62.3 | 1714 | 1.04 (1.03, 1.05) | |
Level of education | ||||
No formal education | 66.4 | 4580 | 1.05 (1.04, 1.06) | 0.16 |
Primary school | 61.6 | 6034 | 1.04 (1.04, 1.05) | |
Secondary school and above | 58.3 | 3691 | 1.04 (1.03, 1.05) | |
Dialect group | ||||
Cantonese | 62.5 | 7519 | 1.04 (1.04, 1.05) | 0.08 |
Hokkien | 62.0 | 6786 | 1.05 (1.04, 1.05) | |
Alcohol consumption, drinks/week | ||||
None | 62.5 | 12,788 | 1.04 (1.04, 1.05) | 0.41 |
< 7 | 60.6 | 1331 | 1.05 (1.04, 1.06) | |
≥ 7 | 62.0 | 186 | 1.06 (1.03, 1.09) | |
Physical activity (weekly) | ||||
No | 62.4 | 10,421 | 1.04 (1.04, 1.05) | 0.71 |
Yes | 61.9 | 3884 | 1.04 (1.04, 1.05) | |
Smoking status | ||||
Never | 61.8 | 13,053 | 1.04 (1.04, 1.05) | 0.87 |
Former | 68.3 | 570 | 1.04 (1.02, 1.06) | |
Current | 66.7 | 682 | 1.04 (1.03, 1.06) | |
Age when period became regular | ||||
< 13 | 59.1 | 1988 | 1.04 (1.04, 1.05) | 0.77 |
13–14 | 61.5 | 5152 | 1.04 (1.04, 1.05) | |
15–16 | 63.5 | 4578 | 1.05 (1.04, 1.05) | |
≥ 17 | 64.7 | 2087 | 1.05 (1.04, 1.05) | |
Never regular | 61.7 | 500 | 1.06 (1.04, 1.08) | |
Age at first live birth | ||||
< 20.0 | 65.6 | 2420 | 1.05 (1.04, 1.06) | 0.42 |
21.0–25.0 | 62.5 | 5357 | 1.04 (1.04, 1.05) | |
26.0–30.0 | 60.8 | 3962 | 1.04 (1.03, 1.05) | |
≥ 31 | 61.0 | 1526 | 1.05 (1.04, 1.06) | |
Nulliparous | 61.3 | 1040 | 1.04 (1.03, 1.06) | |
Number of live births | ||||
0 | 61.2 | 1027 | 1.04 (1.03, 1.05) | 0.07 |
1–2 | 59.3 | 4327 | 1.04 (1.03, 1.05) | |
3–4 | 61.3 | 5748 | 1.04 (1.04, 1.05) | |
≥ 5 | 68.6 | 3158 | 1.05 (1.05, 1.06) | |
Menopausal status | ||||
Premenopausal | 52.6 | 955 | 1.03 (1.02, 1.05) | 0.09 |
Postmenopausal | 63.0 | 13,350 | 1.05 (1.04, 1.05) | |
Age at menopause | ||||
≤ 49 | 69.4 | 2425 | 1.05 (1.04, 1.06) | 0.97 |
50–54 | 68.8 | 3376 | 1.04 (1.04, 1.05) | |
≥ 55 | 57.7 | 8504 | 1.04 (1.04, 1.05) | |
Family history of breast cancer | ||||
No | 62.3 | 14,065 | 1.04 (1.04, 1.05) | 0.20 |
Yes | 60.6 | 240 | 1.06 (1.03, 1.09) | |
Use of hormone therapy | ||||
Never | 63.0 | 11,890 | 1.06 (1.05, 1.08) | 0.82 |
Ever | 59.6 | 1602 | 1.04 (1.03, 1.05) | |
Current | 57.4 | 813 | 1.04 (1.04, 1.05) | |
Use of oral contraceptive | ||||
Never | 63.2 | 9888 | 1.05 (1.04, 1.05) | 0.23 |
Former/current | 60.2 | 4417 | 1.04 (1.03, 1.05) | |
Sleeping hours | ||||
≤ 6 h | 63.2 | 4871 | 1.05 (1.04, 1.05) | 0.04 |
7–8 h | 61.8 | 8503 | 1.04 (1.04, 1.05) | |
≥ 8 h | 62.4 | 931 | 1.03 (1.01, 1.04) | |
Overall mean relative telomere length measure was slightly higher in breast cancer cases (mean 1.07, SD 0.22) than those without breast cancer (mean 1.04, SD 0.23) (P = 0.012). Longer telomeres were significantly associated with a higher risk of breast cancer in a dose-dependent manner after adjustment for age and other potential confounders (Ptrend = 0.006) (Table 3). Compared with the lowest quartile, the highest quartile of telomere length was associated with a statistically significant 47% higher risk of breast cancer (HR = 1.47; 95% CI = 1.11, 1.94). When women were stratified by age and BMI, the associations between telomere length and breast cancer risk were slightly stronger in younger women (< 60 years of age) and in overweight or obese women (BMI ≥ 23 kg/m2) (Table 4). However, the differences in the magnitude of these associations between the contrasting groups were not statistically significant (Ptrend > 0.30).
Table 3
Associations between relative telomere length and risk of breast cancer, the Singapore Chinese Health Study
Telomere length in quartile§ | Cases | Person-years | HR1 (95% CI) | HR2 (95% CI) |
|---|---|---|---|---|
Q1 (0.73–0.85) | 84 | 43,035 | 1.00 (ref) | 1.00 (ref) |
Q2 (0.92–0.99) | 106 | 44,093 | 1.21 (0.91, 1.62) | 1.22 (0.91, 1.62) |
Q3 (1.06–1.13) | 120 | 44,312 | 1.35 (1.02, 1.79) | 1.35 (1.01, 1.78) |
Q4 (1.23–1.40) | 132 | 45,174 | 1.45 (1.09, 1.91) | 1.47 (1.11, 1.94) |
P
trend
| 0.008 | 0.006 |
Table 4
Associations between relative telomere length and risk of breast cancer stratified by age and body mass index, Singapore Chinese Health Study
Telomere length in quartile by stratification variable | Cases | Person-years | Adjusted HR1 (95% CI) | P interaction |
|---|---|---|---|---|
Age (< 60 years) | ||||
Q1 (shortest) | 28 | 12,985 | 1.00 (reference) | 0.30 |
Q2 | 41 | 17,826 | 1.05 (0.65, 1.70) | |
Q3 | 64 | 20,853 | 1.38 (0.88, 2.15) | |
Q4 (longest) | 86 | 25,899 | 1.52 (0.99, 2.33) | |
Ptrend | 0.017 | |||
Age (≥ 60 years) | ||||
Q1 (shortest) | 56 | 30,050 | 1.00 (reference) | |
Q2 | 65 | 26,267 | 1.32 (0.92, 1.89) | |
Q3 | 56 | 23,459 | 1.26 (0.87, 1.82) | |
Q4 (longest) | 46 | 19,275 | 1.27 (0.86, 1.88) | |
Ptrend | 0.25 | |||
Body mass index (< 23.0 kg/m2) | ||||
Q1 (shortest) | 38 | 20,617 | 1.00 (reference) | 0.45 |
Q2 | 44 | 21,321 | 1.12 (0.72, 1.73) | |
Q3 | 46 | 21,377 | 1.14 (0.74, 1.76) | |
Q4 (longest) | 55 | 22,407 | 1.31 (0.86, 2.01) | |
Ptrend | 0.21 | |||
Body mass index (≥ 23.0 kg/m2) | ||||
Q1 (shortest) | 46 | 22,417 | 1.00 (reference) | |
Q2 | 62 | 22,772 | 1.32 (0.90, 1.94) | |
Q3 | 74 | 22,935 | 1.51 (1.04, 2.19) | |
Q4 (longest) | 77 | 22,766 | 1.59 (1.09, 2.32) | |
Ptrend | 0.013 | |||
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We performed a sensitivity analysis by dividing breast cancer cases with various number of years from blood draw to cancer diagnosis to evaluate if the underlying subclinical disease progression had any impact on telomere length and so on the association between telomere length and risk of breast cancer (Table 5). For women with less than 5 years of follow-up, HR (95% CI) of breast cancer incidence for the highest compared to the lowest quartile of telomere length was 1.68 (1.05–2.69) (Ptrend = 0.015). The corresponding figure for women with five or more years of follow-up was 1.35 (0.95–1.92) (Ptrend = 0.12). However, P for heterogeneity in comparison of the two hazard ratios was not statistically significant (P = 0.47). As shown in Additional file 1: Table S2, when we limited the sensitivity analysis to breast cancer cases diagnosed during the first 2 years of follow-up, a similar result was found (P for heterogeneity = 0.32).
Table 5
Associations between relative telomere length and risk of breast cancer stratified by length of follow-up, Singapore Chinese Health Study
Telomere length in quartile by stratification variable | Cases | Person-years | Adjusted HR1 (95% CI) |
|---|---|---|---|
Follow-up < 5 years | |||
Q1 (shortest) | 29 | 17,272 | 1.00 (reference) |
Q2 | 42 | 17,329 | 1.42 (0.89, 2.29) |
Q3 | 58 | 17,298 | 1.95 (1.24, 3.06) |
Q4 (longest) | 50 | 17,353 | 1.68 (1.05, 2.69) |
Ptrend | 0.015 | ||
Follow-up ≥ 5 years | |||
Q1 (shortest) | 55 | 25,763 | 1.00 (reference) |
Q2 | 64 | 26,764 | 1.11 (0.77, 1.59) |
Q3 | 62 | 27,014 | 1.04 (0.72, 1.50) |
Q4 (longest) | 82 | 27,821 | 1.35 (0.95, 1.92) |
Ptrend | 0.12 | ||
Discussion
We investigated the association between white blood cell telomere length and breast cancer risk in a prospective study of 14,305 middle-aged or older Chinse women in Singapore. Our results showed that women in the top quarter of telomere length had a statistically significant 47% higher risk of breast cancer than women in the bottom quarter of telomere length after adjustment for age and other potential confounders. The positive association between telomere length and risk of breast cancer was in a dose-dependent manner.
We used peripheral blood leukocytes as the surrogate for breast tissue, which may have different telomere length. Studies have shown that telomere lengths varied considerably across different tissue types but were strongly correlated with one another within a person [35‐37]. In addition, Daniali et al. [38] have reported that the rate of telomere shortening in somatic tissues was similar for different tissue types. There have been no studies that directly evaluated the correlation between telomere length in white blood cells and breast tissue.
Four prior case-cohort or nested case-control studies within prospective cohorts also reported mixed results. Three of the four studies in the USA and the UK found no significant association between telomere length and risk of breast cancer incidence [20, 22, 24]. The other study in a Chinese population reported that shorter telomeres were associated with significantly higher risk of breast cancer [21]. There has been only one prospective cohort study that examined telomere length and risk of breast cancer and other specific cancer sites [23]. The cohort included more than 65,000 Danish women and found that longer telomeres in peripheral leukocytes were associated with a higher but statistically non-significant risk of breast cancer [23]. Our study found a statistically significant association between long telomeres and high risk of breast cancer in Chinese women in Singapore. Previous studies suggested that the discrepancies in the associations between telomere length and disease risk might have resulted from different methods used for DNA extraction and/or telomere length measurement [39, 40]. In our study, we used the same Qiagen DNA extraction method and the same qPCR assay for telomere length as the 5 studies described above except for one study [20] that the DNA extraction method was not described. Thus, the discrepancy in the results of ours from previous studies may not be explained by the DNA extraction and telomere length measurement methods. The discrepancy may be due to the different study populations and/or study design. Our findings warrant further studies for confirmation.
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To date, two Mendelian randomization studies [41, 42] have investigated the possible causal relation between genetic variants associated with telomere length and risk of different cancer types including breast cancer. These studies yielded a null association between telomere length-associated single nucleotide polymorphisms (SNPs) and risk of breast cancer. Although Mendelian randomization studies potentially minimized the potential environmental confounding factors on telomere length, they could have the drawbacks of pleiotropic effects and population stratification biases.
Little is known about the potential biological mechanisms through which telomere influences breast cancer risk. In general, cells with very short telomeres may induce replicative senescence or apoptosis, which suppress the proliferative potential of a cell and, thus, lend support to a tumor-suppressor activity [7, 43]. On the other hand, telomere lengthening in women with breast cancer or basal-type breast cancer cells has been associated with genetic variations in genes encoding telomere-related proteins [44, 45] and epigenetic silencing of miR-296 and miR-512 genes expression [46], respectively. The hormonal effect has also been suggested as another explanation for longer telomeres and increased risk of breast cancer since estrogen is directly implicated in activation of telomerase via effects on human telomerase reverse transcriptase (hTERT) promoter [47] and post-transcriptional modification through Akt-dependent phosphorylation of hTERT [48]. However, previous observational reports, either case-cohort [22] or case-control studies [13‐15], found no significant association between telomere length and breast cancer risk by hormone receptor status yet large prospective cohort studies with quantified estrogen levels are required to shed light on the role of sex steroid hormones in the relationship with telomere length.
Several strengths of the current study are noteworthy. This is the first prospective cohort study conducted in an ethnically homogenous population in Eastern Asia. In addition, exposure assessment (i.e., telomere length measurement) was performed on samples from all cohort women who provided blood prior to the diagnosis of breast cancer; thus, reverse causality bias is not a concern in our findings. The study also took advantage of a long duration of follow-up. Finally, the Singapore population-based Cancer Registry, as a nationwide program, has been recording cancer cases for more than the last 50 years, and therefore, breast cancer case ascertainment should be essentially complete [49]. There are some limitations to the present study. Although we collected extensive information on known environmental and lifestyle risk factors for breast cancer prior to cancer diagnosis at study enrollment, we cannot rule out the possibility of residual confounding effects. Another limitation is the relatively small sample size of breast cancer cases, particularly in stratification analyses. We did not also evaluate telomere length in relation to estrogen concentrations or hormone receptor status in the present analysis since these data were only available for a very small subset of cases, and therefore, we had limited statistical power to detect a meaningful risk estimate. Lastly, these results may not be generalizable to other ethnic groups or premenopausal women since approximately 93% of the breast cancer cases in our study were postmenopausal. Our findings require confirmation in other large cohorts of the Asian population.
Conclusions
In conclusion, the results of this study show that longer prediagnostic telomere length in blood leukocytes is significantly associated with an enhanced risk of breast cancer in a stepwise manner among a predominantly postmenopausal Asian women population. Our findings provide further evidence that leukocyte telomere length has the potential to act as a moderate risk factor for breast cancer. Whether telomere length can be implemented as a biomarker for breast cancer risk prediction warrants replication in additional large prospective cohort studies with diverse populations.
Acknowledgements
The authors thank Siew-Hong Low of the National University of Singapore for supervising the fieldwork of the Singapore Chinese Health Study; Kenneth Beckman, Shalane Porter and Dinesha Walek of the University of Minnesota Genetic Center for their assistance in measurement of telomere length; the Singapore Cancer Registry for the identification of cancer cases and the Singapore Chinese Health Study subjects for their participation in this study.
Funding
This work was supported by NIH/NCI (R01 CA144034 and UM1 CA182876); H. Samavat was supported by the NIH/NCI T32CA186873 training grant in cancer epidemiology; W-P Koh was supported by the National Medical Research Council, Singapore (NMRC/CSA/0055/2013) grants.
Availability of data and materials
The dataset analyzed in the current study is available from the corresponding author on reasonable request.
Ethics approval and consent to participate
All study participants provided written informed consent. The institutional review boards of the National University of Singapore and the University of Pittsburgh approved the study.
Consent for publication
Not applicable.
Competing interests
The authors declare that they have no competing interests.
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