A number of studies have investigated the association between reproductive factors and lung cancer risk, however findings are inconsistent. This meta-analysis aimed to evaluate the association between female reproductive factors and lung cancer risk.
Methods
We conducted a comprehensive systematic search to identify relevant and eligible studies published before 18th December 2019. Inter-study heterogeneity was assessed using the Q test and I2 statistic. Based on the heterogeneity of each reproductive factor, fixed or random effects models were used to calculate the summary odds ratios (ORs) and 95% confidence intervals (CIs). Subgroup analyses by study design, lung cancer subtypes, smoking status, and ethnicity were also performed.
Results
A total of 66 studies with 20 distinct reproductive factors were included in this meta-analysis. Comparing the highest and lowest categories (reference) of each reproductive factor, parity (OR = 0.83, 95% CI = 0.72–0.96), menstrual cycle length (OR = 0.79, 95% CI = 0.65–0.96), and age at first birth (OR = 0.85, 95% CI = 0.74–0.98), were significantly associated with a lower risk of overall lung cancer. On the contrary, non-natural menopause was significantly associated with higher lung cancer risk (OR = 1.52, 95% CI = 1.25–1.86). Among never-smokers, a significant negative association was found between parity and lung cancer risk. Both parity and non-natural menopause were statistically significant in case-control studies.
Conclusion
These results suggest that certain reproductive factors may be associated with lung cancer risk. Future studies should further validate the associations, and investigate the underlying mechanisms.
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Abkürzungen
OR
Odds ratio
CI
Confidence interval
EGFR
Epidermal growth factor receptor
CNKI
Chinese National Knowledge Infrastructure
AC
Adenocarcinoma
SCC
Squamous cell carcinoma
SCLC
Small-cell lung cancer
NSCLC
Non-small-cell lung cancer
RR
Risk ratio
SIR
Standardized incidence ratio
HR
Hazard ratio
EPT
Estrogen plus progestin
E
Estrogen alone
HRT
Hormone replacement therapy
ER
Estrogen receptor
NOS
Newcastle-Ottawa Scale
CRBT
Cochrane Risk of Bias Tool
PRISMA
Preferred Reporting Items for Systematic Reviews and Meta-Analyses
Background
Lung cancer is the leading cause of cancer death worldwide among both men and women [1]. Despite cigarette smoking being the predominant carcinogen for lung cancer risk, it only contributes to approximately half of the lung cancer cases among women, since most women are never-smokers [2]. Among never smokers, the rate of lung cancer incidence was reported to be higher in women than in men [3], and a reduction in smoking prevalence decreased lung cancer mortality rate in men, but not in women [4]. Studies have suggested that women, by being more susceptible to carcinogens in tobacco smoke [5, 6], may have a higher chance of developing lung cancer at a younger age and with less smoking intensity than men [7‐9].
Reproductive and hormonal factors have been hypothesized to be influential stimuli to lung cancer carcinogenesis. Previous studies have detected estrogen receptors in both normal and cancerous lung tissues [10, 11], higher rates of epidermal growth factor receptor (EGFR) mutation-positive lung cancer in never-smoking women [12], familial aggregation of reproductive cancers among female lung cancer patients [13, 14], and increased lung cancer risk in female cancer survivors with a history of reproductive-related primary tumors [15‐21]. However, results from epidemiological studies investigating the relationship between hormonal and reproductive factors with lung cancer risk are conflicting. For example, some studies suggested a significant decrease of female lung cancer risk with increased parity [22‐24] or hormone use [25‐27], whereas other studies reported the opposite, a positive association between increased parity [28, 29] or hormone use [30, 31] and lung cancer risk.
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To evaluate the association between female reproductive factors and lung cancer risk, we conducted a comprehensive systematic review and meta-analysis and stratified by ethnicity, smoking status, study design, and histology.
Methods
Literature search and identification of eligible studies
A systematic literature search was performed by two independent reviewers using the following search terms: reproductive, estrogen, hormone, birth, menopause, menarche, oral contraceptive, parity, pregnancy AND women AND lung cancer, using PubMed, Chinese National Knowledge Infrastructure (CNKI), National University of Singapore Library, and Google Scholar databases before December 2019, restricted to English and Chinese language papers. The detailed search strategy was developed for PubMed and adapted for other databases (Supplementary Table S1). Relevant publications from the reference lists of identified papers were also extensively reviewed to include additional studies in order to avoid missing any potential publications during the database search. Studies were scrutinized for their eligibility to be included in our analysis using the following inclusion criteria: 1) the study design was either case-control, cohort, or randomized controlled trial; 2) the outcome of interest was either overall lung cancer or lung cancer subtypes (adenocarcinoma (AC), squamous cell carcinoma (SCC), small cell lung cancer (SCLC) and non-small-cell lung cancer (NSCLC)); 3) the exposure variables were related to reproductive, menstrual, or hormonal factors; 4) if there were repeated studies published by the same group of authors, only the most recently updated publication was included, unless different study designs were used. Studies were excluded if they did not specify the reference group used, reference group overlapped, or if they did not include a measure of association.
Data extraction
Information was extracted from each of the selected studies and recorded as the following variables: last name and initial of first name of the first author, publication year, journal name, reproductive factors, non-reference (the highest or the lowest) and reference group, study population (e.g., Asian, Caucasian, or Mixed), lung cancer subtype (AC, SCC, NSCLC or SCLC), study design (case-control, cohort, randomized clinical trial), number of cases and controls, smoking status (if applicable, never smokers, past smokers, current smokers), presence of EGFR mutation (if applicable), association estimates (odds ratios (ORs) or risk ratios (RRs) for case-control studies, risk ratios (RRs), standardized incidence ratios (SIRs) or hazard ratios (HRs) for cohort studies), 95% confidence intervals (CIs) and P-values for the non-reference group (for categorical variables) or for the continuous interval (for continuous variables), or P-trend with the corresponding statistical adjustments. As hormone replacement therapy type medications were reported in many different ways, including estrogen plus progestin (EPT), estrogen alone (E), hormone replacement therapy (HRT), hormone use, and postmenopausal hormone therapy, we combined them into an ever/never use of hormones variable; women with current and former smoking status were combined as “ever smokers” category. We recalculated the overall total effect using meta-analyses if the original paper only provided the separate effect for these single categories.
Statistical analysis
Pooled estimates were calculated as the inverse variance-weighted mean of the logarithm of OR with 95% confidence interval (CI) to assess the association between reproductive factors and lung cancer risk. Heterogeneity among the included studies was evaluated using the Q test, and I2 statistic that represents the proportion of total variation attributable to inter-study heterogeneity. In the presence of substantial heterogeneity (I2 > 50%) [32], the random effects model was used as the pooling method; otherwise, the fixed effects model was applied. We also stratified the meta-analysis by study design (case-control, cohort or randomized clinical trial), lung cancer subtypes (overall lung cancer, AC or NSCLC), smoking status (never smokers or ever smokers), and ethnicity (Asian, Caucasian, or Mixed) for reproductive factors.
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Assessment for potential publication bias was conducted using Egger’s linear regression analysis and trim-and-fill method. The ‘leave one out’ sensitivity analysis was carried out to assess potential heterogeneity and the robustness of the findings [33, 34].
To assess the quality of our included studies, we performed the Newcastle-Ottawa Scale (NOS) for observational studies and the Cochrane Risk of Bias Tool (CRBT) assessment for randomized controlled trials. For those studies with poor quality and high risk of bias (NOS score ≤ 5 or CRBT score < 4), we excluded them for the sensitivity analysis.
This meta-analysis followed the Preferred Reporting Items for Systematic Reviews and Meta-Analyses (PRISMA) guidelines [35]. All statistical analysis was conducted using Stata version 15.0 (Stata Corporation, College Station, Texas, USA). All statistical tests were conducted as two-sided, and a P-value of < 0.05 was considered as being statistically significant.
Results
The literature search identified 2050 publications from the databases and 3 additional studies were retrieved from the reference lists of previous meta-analysis studies that were identified through the search terms. A total of 133 duplicates, 1791 irrelevant publications, and 63 studies with full-text screening were excluded. Finally, 66 studies were eligible for inclusion into this meta-analysis [22‐28, 31, 36‐93] (Fig. 1). The characteristics of the 66 selected studies are shown in Supplementary Table S2, Additional file 1. In total, there were 25 cohort studies, 37 case-control studies, and four randomized controlled trials. The publication years of these studies ranged from 1987 to 2019. Collectively, 26 studies were conducted among Asian females, 25 studies among Caucasian females, and 15 studies among mixed ethnicities. Of the 66 selected studies, 20 studies further stratified by smoking status, and 23 studies stratified by lung cancer subtypes (AC, SCC, NSCLC or SCLC). A total of 31 reproductive factors were extracted from the selected studies, with 20 reproductive factors included in the meta-analysis after combining some of the factors due to the sparse number of eligible studies (Table 1 and Fig. 1). Among these exposures, we found statistical significance for four reproductive variables with overall lung cancer risk: parity, age at first birth, non-natural menopause, and menstrual cycle length (Fig. 2). Other forest plots are shown in Supplementary Fig. S1, Additional file 2.
Fig. 1
Flowchart of study selection, inclusion, and analysis
Table 1
Association of reproductive factors and overall lung cancer risk (highest vs. lowest category)
Reproductive factors
Highest category
Lowest category (reference)
No. of studies
Pheta
I2 value (%)
OR (95% CI)b
Menstrual-related factors
Age at menopause
≥50 to ≥55
Premenopausal or < 50
22
< 0.001
64.3
0.99 (0.88, 1.12)
Age at menarche
≥15 to ≥18
< 11 to ≤15
20
0.032
40.4
1.03 (0.96, 1.10)
Non-natural menopause
Non-natural
Natural / premenopausal
11
0.013
55.3
1.52 (1.25, 1.86)
Ovariectomy
yes
no
5
0.487
0.0
1.38 (1.16, 1.64)
Hysterectomy
yes
no
4
0.171
40.1
1.21 (0.98, 1.49)
Ovariectomy and Hysterectomy
yes
no
4
0.405
0.0
1.22 (0.95, 1.58)
Menstrual cycle length
> 30 days
< 27 to ≤ 30 days
7
0.106
42.7
0.79 (0.65, 0.96)
Menopausal status
Post-menopausal
Pre-menopausal
6
0.057
53.4
1.26 (0.92, 1.73)
Length of menstrual flow (days)
≥5 to > 6
≤3 to < 5
4
0.712
0.0
1.01 (0.84, 1.23)
Other factors
Hormone use
ever
never
38
< 0.001
56.6
0.95 (0.90, 1.01)
Oral contraceptive use
ever
never
26
0.003
48.2
1.01 (0.94, 1.09)
OC use duration (years)
≥2 to ≥12
0 to < 2
12
0.012
54.5
0.99 (0.87, 1.14)
Parity
≥3 to ≥ 7
0 to 2
24
< 0.001
75.4
0.83 (0.72, 0.96)
Number of pregnancy
≥ 4 to ≥7
0 to 2
10
0.002
66.3
0.91 (0.73, 1.15)
Age at first birth
≥25 to ≥ 31
Nulliparous or < 25
19
< 0.001
62.7
0.85 (0.74, 0.98)
Reproductive period (years)
≥36 to ≥41
≤30 to < 33
8
0.048
50.6
0.95 (0.78, 1.17)
Breastfeeding
ever
never
6
0.330
13.2
0.94 (0.83, 1.06)
Miscarriage
ever
never
4
0.063
58.9
1.20 (0.93, 1.56)
Tubal sterilization use
ever
never
4
0.019
69.7
1.05 (0.84, 1.33)
Intrauterine device use
ever
never
4
0.097
52.5
0.83 (0.66, 1.04)
aHeterogeneity P-value
bAdjusted odds ratio (OR) and 95% confidence interval (CI). Highest non-reference category as compared to the lowest reference group
Fig. 2
Significant associations between reproductive variables and overall lung cancer risk
×
×
Parity
Twenty-four studies reported the association between parity and overall lung cancer risk. A total of 10 studies stratified by lung cancer subtypes. The highest parity category ranged from ≥3 to ≥7 children, while the lowest parity category ranged from 0 to 2 children. The pooled ORs were 0.83 (95% CI = 0.72–0.96, I2 = 75.4%) for overall lung cancer, 0.84 (95% CI = 0.63–1.11, I2 = 75.1%) for NSCLC, and 0.83 (95% CI = 0.63–1.09, I2 = 67.0%) for adenocarcinoma (Tables 1 and 2). Specifically, a significant negative association of higher parity and overall lung cancer risk was found among Asians (OR = 0.70, 95% CI = 0.58–0.86, I2 = 59.7%), but no association was observed among Caucasians. After further stratification by study design, and lung cancer subtype, higher parity was significantly associated with decreased risks of overall lung cancer (OR = 0.58, 95% CI = 0.44–0.75, I2 = 45.3%), non-small cell lung cancer (OR = 0.39, 95% CI = 0.18–0.84, I2 = 25.3%) and lung adenocarcinoma (OR = 0.45, 95% CI = 0. 28–0.71, I2 = 30.0%) among Asian women in cohort studies.
Table 2
Association of significant reproductive factors and lung cancer risk, stratified by subgroups (highest vs. lowest category)
Reproductive factorsa
n
OR (95% CI)b
Case-Control
Cohort
n
OR (95% CI)b
n
OR (95% CI)b
Parity (highest vs. lowest)
Overall lung cancer
24
0.83 (0.72, 0.96)
15
0.82 (0.68, 0.98)
9
0.85 (0.68, 1.05)
Asian
12
0.70 (0.58, 0.86)
7
0.81 (0.65, 1.01)
5
0.58 (0.44, 0.75)
Caucasian
8
1.03 (0.85, 1.25)
5
0.93 (0.60, 1.43)
3
1.12 (0.96, 1.31)
Adenocarcinoma
10
0.83 (0.63, 1.09)
5
1.00 (0.82, 1.22)
5
0.71 (0.43, 1.16)
Asian
5
0.72 (0.37, 1.39)
2
1.22 (0.86, 1.73)
3
0.45 (0.28, 0.71)
Caucasian
4
0.93 (0.76, 1.13)
2
0.74 (0.44, 1.24)
2
0.97 (0.78, 1.20)
Non-small cell lung cancer
10
0.84 (0.63, 1.11)
5
0.81 (0.51, 1.29)
5
0.85 (0.57, 1.27)
Asian
4
0.82 (0.33, 2.07)
2
1.22 (0.86, 1.73)
2
0.39 (0.18, 0.84)
Caucasian
4
0.94 (0.69, 1.29)
2
0.74 (0.44, 1.24)
2
0.97 (0.78, 1.20)
Never Smokers
11
0.71 (0.54, 0.93)
5
0.65 (0.52, 0.81)
6
0.80 (0.51, 1.28)
Asian
7
0.65 (0.54, 0.78)
Caucasian
2
0.99 (0.25, 3.85)
Ever Smokers
8
0.78 (0.59, 1.04)
4
0.56 (0.41, 0.75)
4
1.01 (0.76, 1.34)
Asian
4
0.54 (0.40, 0.75)
Caucasian
2
1.14 (0.92, 1.40)
Parity (highest vs. nulliparous)
Overall lung cancer
16
0.77 (0.62, 0.95)
10
0.79 (0.62, 1.00)
6
0.72 (0.49,1.06)
Asian
5
0.56 (0.47, 0.67)
1
0.61 (0.43, 0.87)
4
0.55 (0.45, 0.66)
Caucasian
8
0.96 (0.73, 1.26)
6
0.83 (0.58, 1.18)
2
1.22 (0.97, 1.52)
Adenocarcinoma
8
0.71 (0.49, 1.01)
4
0.83 (0.64, 1.08)
4
0.66 (0.31, 1.41)
Asian
3
0.45 (0.28, 0.71)
3
0.45 (0.28, 0.71)
Caucasian
4
0.84 (0.52, 1.35)
3
0.66 (0.45, 0.98)
1
1.41 (0.90, 2.20)
Age at first birth
Overall lung cancer
19
0.85 (0.74, 0.98)
12
0.77 (0.61, 0.97)
7
0.94 (0.81, 1.08)
Asian
9
0.90 (0.66, 1.22)
Caucasian
6
0.75 (0.65, 0.88)
Adenocarcinoma
10
0.84 (0.74, 0.95)
6
0.85 (0.72, 1.00)
4
0.82 (0.67, 1.01)
Asian
3
0.62 (0.47, 0.83)
Caucasian
5
0.82 (0.68, 0.97)
Non-natural menopause
Overall lung cancer
11
1.52 (1.25, 1.86)
6
1.83 (1.50, 2.22)
5
1.17 (1.00, 1.37)
Asian
4
1.36 (1.07, 1.72)
Caucasian
5
1.67 (1.12, 2.49)
Adenocarcinoma
6
1.41 (1.18, 1.69)
5
1.64 (1.25, 2.14)
1
1.24 (0.97, 1.59)
Caucasian
5
1.44 (1.19, 1.74)
Menstrual cycle length
Overall lung cancer
7
0.79 (0.65, 0.96)
7
0.79 (0.65, 0.96)
Asian
3
0.64 (0.49, 0.85)
Caucasian
4
0.98 (0.74, 1.28)
Adenocarcinoma
4
0.79 (0.55, 1.14)
4
0.79 (0.55, 1.14)
Caucasian
3
0.79 (0.51, 1.21)
aSubgroup analyses were conducted if there were at least four studies published for that reproductive variable
bAdjusted odds ratio (OR) and 95% confidence interval (CI). Highest non-reference category as compared to the lowest reference group
Eleven studies assessed parity and lung cancer risk among never-smokers while 8 studies assessed the association among ever-smokers. For overall lung cancer, the ORs for Asian women were 0.65 (95% CI = 0.54–0.78, I2 = 0.0%) among never-smokers and 0.54 (95% CI = 0.40–0.75, I2 = 0.0%) among ever smokers. Among case-control studies, higher parity was also significantly negatively associated with overall lung cancer risk among never smokers (OR = 0.65, 95% CI = 0.52–0.81, I2 = 0.0%).
Relative risk estimates of ever parous (≥1 child versus nulliparous) were reported in 16 lung cancer studies and 8 adenocarcinoma studies. We also found a significant negative association between parity and overall lung cancer risks among Asian women in both case-control and cohort studies (OR = 0.56, 95% CI = 0.47–0.67, I2 = 11.4%). Forest plots of subgroup analyses are shown in Supplementary Figs. S2-S8, Additional file 2.
Age at first birth
Relative risk estimates for age at first birth were reported in 19 studies for overall lung cancer and 10 studies for adenocarcinoma (oldest age group versus youngest age group). The highest age at first birth category ranged from ≥25 to ≥31, and the lowest reference age at first birth category ranged from nulliparous to < 25. The pooled ORs were 0.85 (95% CI = 0.74–0.98, I2 = 62.7%) and 0.84 (95% CI = 0.74–0.95, I2 = 36.9%) for overall lung cancer and adenocarcinoma risk for older age at first birth, respectively (Tables 1 and 2). Among Asian women, older age at first birth was significantly negatively associated with adenocarcinoma risks (OR = 0.62, 95% CI = 0.47–0.83, I2 = 0.0%). Among Caucasian women with older age at first birth, overall lung cancer risk (OR = 0.75, 95% CI = 0.65–0.88, I2 = 15.9%) was significantly lower than those with younger age at first birth, but this association was not significant among Asian women. We did a sensitivity analysis by excluding the nulliparous women to avoid conflating the effects of parity and age at first birth (only one study was excluded), and the result did not change (OR = 0.83, 95% CI = 0.72–0.96, I2 = 61.7%). Forest plots of subgroup analyses are shown in Supplementary Fig. S9, Additional file 2.
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Non-natural menopause
Relative risk estimates for non-natural menopause versus natural menopause were reported in 11 studies for overall lung cancer (OR = 1.52, 95% CI =1.25–1.86, I2 = 55.3%) and in 6 studies for adenocarcinoma (OR = 1.41, 95% CI =1.18–1.69, I2 = 0.0%) (Tables 1 and 2). Non-natural menopause was significantly associated with higher overall lung cancer risk, particularly among Caucasian women for overall lung cancer (OR = 1.67, 95% CI =1.12–2.49, I2 = 73.4%) and lung adenocarcinoma (OR = 1.44, 95% CI =1.19–1.74, I2 = 0.0%). A significant positive association with overall lung cancer risk was found among women with ovariectomy (OR = 1.38, 95% CI =1.16–1.64, I2 = 0.0%) (Supplementary Fig. S1, S10, Additional file 2).
Menstrual cycle length
The highest menstrual cycle length category was defined as more than 30 days, and the lowest reference menstrual cycle length category ranged from < 27 to ≤30 days. The association between menstrual cycle length (highest vs. lowest category) and lung cancer risk was reported in 7 studies for overall lung cancer (OR = 0.79, 95% CI = 0.65–0.96, I2 = 42.7%) and in 4 studies for adenocarcinoma (OR = 0.79, 95% CI = 0.55–1.14, I2 = 0.0%) (Tables 1 and 2). Longer menstrual length was significantly associated with lower lung cancer risks among Asian women (OR = 0.64, 95% CI = 0.49–0.85, I2 = 0.0%) (Supplementary Fig. S11, Additional file 2).
Publication bias
Publication bias was assessed using Egger’s test, if there were at least 10 studies on the reproductive factor [94]. Results of Egger’s test showed that studies among parity and menopause type may have publication bias (Table 3). This suggested the presence of a potential publication bias, a language bias, inflated estimates by a flawed methodologic design in smaller studies, and/or a lack of publication of small trials with opposite results. Therefore, we conducted the ‘leave one out’ sensitivity analysis to explore the heterogeneity among studies of parity and menopause type, and no individual study was found to have excessive influence on the pooled effect (Supplementary Fig. S12, Additional file 2).
Table 3
Egger’s test for publication bias assessment (number of studies ≥10)
Variables
No. of studies
P value of Egger’s test
Hormone use
38
0.498
OC use
26
0.565
Parity
24
0.041
Age at menopause
22
0.984
Age at menarche
20
0.841
Age at first birth
19
0.895
Parity with nulliparous women as reference
16
0.110
OC use duration
12
0.112
Menopause type
11
0.014
Number of pregnancy
10
0.559
Sensitivity analysis
In addition, we used the trim and fill method to test publication bias that conservatively imputes hypothetical negative unpublished studies to mirror the positive studies that cause funnel plot asymmetry. The imputed studies produce a symmetrical funnel plot (Supplementary Fig. S13, Additional file 2). The pooled analysis incorporating the hypothetical studies continued to show a statistically significant association between parity, menopause type, and lung cancer risk.
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We assessed the quality of all the included studies by removing 7 studies with poor quality and a high level of bias (NOS score ≤ 5 or CRBT score < 4) for the sensitivity analysis (Supplementary Table 3–9, Additional file 1). The results did not change except for hormone use, and the effect of hormone use changed from borderline non-significant (OR = 0.95, 95% CI = 0.90–1.01, I2 = 56.6%) to borderline significant (OR = 0.93, 95% CI = 0.88–0.99, I2 = 55.4%).
Discussion
Our meta-analysis of 20 reproductive factors revealed significant associations between parity, non-natural menopause, menstrual cycle length, and age at first pregnancy on lung cancer risk. Higher parity, older age at first pregnancy, and longer menstrual cycle length were associated with lower lung cancer risk. Conversely, non-natural menopause such as ovariectomy was found to be associated with higher risk of lung cancer.
Previous meta-analysis studies reported no significant associations between parity and lung cancer risk, regardless of ethnicity or study design [95, 96]. However, the number of included studies and different methods of calculating the risk ratios may account for the discrepancy. Two previous meta-analysis studies included a total of up to 21 studies before 2012 [95, 96]. They combined the estimates of the number of pregnancy and live birth, and Dahabreh et al.’s meta-analysis study [95] used both continuous and categorical risk estimates from published studies. In contrast, for parity, our meta-analysis only used categorical relative risk estimates extracted from 24 published studies and included 8 recent new studies after 2012 in addition to all the other studies that were included in the previous two meta-analyses. Relative risk estimates for the number of pregnancies and overall lung cancer risk reported by eight studies were included as an independent variable in our meta-analysis. Similar to Zhang et al. [96], we also found a significant negative association of lung cancer risk among women with longer menstrual cycle length. Shorter menstrual cycle length may increase the period of endogenous estrogen exposure (follicular phase), followed by increased cumulative exposure [97]. However, a previous meta-analysis found no significant association between older age at first birth and lung cancer risk [96].
There are several proposed mechanisms that have been hypothesized to explain the relationship between reproductive factors and the risk of lung cancer. Collectively, these factors are ascribed to the potential effects of estrogen on lung cancer risk. The hormonal etiology may play a direct role in the development of lung cancer. Estrogen and progesterone were associated with lung tumor proliferation, a process that can be triggered by hormonal receptors including estrogen receptors (ERs), progesterone, and epidermal growth factor (EGFR) receptors [98]. These receptors were found to be expressed in lung tumors [99, 100] and normal lung tissues [101], and they demonstrated regulatory effects in tumor growth and proliferation [10, 102‐104]. Progesterone- receptors were reported to have tumor-suppressive effects, [105] while estrogen receptors were shown to stimulate tumor proliferation [106, 107]. Estrogen levels among women with lung cancer are usually higher than those in women without lung cancer [108]. Estrogenic stimulation in a murine xenograft model produced proliferative responses in lung tumor cell lines and increased tumor volumes [11]. Previous studies also reported that estrogen β receptors promote estrogen-dependent growth of lung cancer cells [109, 110]. In our study, we found negative associations between higher parity, older age at first pregnancy, and longer menstrual cycle length with lung cancer risk. Consistent with the proposed mechanisms, these protective reproductive factors are associated with lower estrogen levels in women [97, 111, 112].
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Furthermore, estrogen can directly stimulate the transcription of estrogen-responsive genes in the nucleus of lung cells, and transactivate growth factor signaling pathways, in particular the epidermal growth factor pathway [100, 113]. EGFR mutations often occur among adenocarcinoma lung cancer subtypes, females, never-smokers, and East Asians [114‐117]. In our study, we observed lower lung cancer risk among never-smokers and Asian women with higher parity, suggesting that higher parity is inversely associated with lung cancer risk by inhibiting EGFR activation or mutation. Estrogens may also influence lung carcinogenesis by their effect on carcinogen metabolism via the cytochrome P450 enzyme system [100].
We also found that non-natural menopause, including ovariectomy, was positively associated with lung cancer risk. However, the potential mechanisms remain unclear. This may be due to a sudden drop in circulating hormone levels after bilateral ovariectomy, unlike natural menopausal women whose circulating hormone levels decline gradually [65, 118, 119]. In addition, women with surgical menopause are usually placed on long-term hormone replacement therapy, which was previously shown to be associated with lung cancer risk [120]. However, there are controversies in the association between hormone replacement therapy and lung cancer risk [113].
Our meta-analysis has several limitations. First, we were unable to assess the dose-response effect or further stratify by other, or less common lung cancer histology types for most reproductive factors (e.g., squamous cell carcinoma, small cell lung cancer) because there were inadequate number of studies for such analyses. Second, the existing studies used different terms to describe hormone use (e.g., hormone replacement therapy, hormone therapy, postmenopausal hormone use, estrogen use, conjugated estrogen use, estrogen replacement use), thus we combined them and examined the overall association of hormone use on lung cancer risk. Hence, we may not be able to delineate the differential associations of the different hormone types. Third, given the different cutoffs used for reference category and confounder adjustments across different studies, our results might include trivial disparity and instability when evaluating the true impact of reproductive factors on lung cancer risk. Fourth, this analysis can only draw an inference on association of the reproductive factors with lung cancer risk, and not the cause-effect relationship. Finally, our inclusion of only published articles that were written either in English or in Chinese, and the exclusion of potentially relevant papers that were not publicly available may influence the publication bias of our study [121, 122].
Despite some of the existing limitations in our study, this is the first study to include a comprehensive review and meta-analysis of 20 reproductive factors, provide detailed stratification on each of the reproductive factor by lung cancer subtype, smoking status, ethnicity and study design, and assess the association between certain reproductive factors such as breastfeeding, ovariectomy, miscarriage, tubal sterilization use, reproductive period, length of menstrual flow, hysterectomy, intrauterine device use, and lung cancer risks among women.
Conclusions
In conclusion, we found a significant protective effect of higher parity, older age at first pregnancy, and longer menstrual cycle length on lung cancer risk, but a significant positive association between non-natural menopause with lung cancer risk. Increased parity had a negative association with lung cancer risk among never-smoking women. Future studies should validate the association between reproductive and menstrual exposures on lung cancer risks and investigate the underlying mechanisms.
The authors declare that they have no competing interests.
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