Quantitative assessment of aberrant P16INK4a methylation in ovarian cancer: a meta-analysis based on literature and TCGA datasets.

Epigenetic alteration of P16INK4a is conventionally thought to induce the initiation of carcinoma. However, the role of P16INK4a methylation in ovarian cancer still remains controversial. Therefore, we performed a meta-analysis to further elucidate the relationship between P16INK4a promoter methylation and ovarian cancer. A total of 24 studies, including 20 on risk, 10 on clinicopathological features, and 3 on prognosis, were included in our meta-analysis. Our results indicated that the frequency of P16INK4a methylation in cancer tissues was significantly higher than normal tissues and low malignant potential tumor tissues (odds ratio [OR] =5.01, 95% CI=1.55-16.14; OR =1.88, 95% CI=1.10-3.19, respectively), but similar to benign tissues (OR =1.18, 95% CI=0.52-2.65). Furthermore, P16INK4a promoter methylation was not strongly correlated with age, clinical stage, tumor differentiation, or histological subtype in patients with ovarian cancer. Additionally, survival analysis showed that patients with P16INK4a promoter methylation had a shorter progression-free survival in univariate and multivariate Cox regression models (hazard ratio =1.68, 95% CI=1.26-2.24; hazard ratio =1.55, 95% CI=1.15-2.08; respectively). In The Cancer Genome Atlas datasets, the methylation levels of seven out of nine CpG sites were significantly increased in the ovarian tumor tissues compared with the normal tissues. In conclusion, the present meta-analysis suggests that P16INK4a promoter methylation may be useful in distinguishing malignant cancer from healthy ovarian tissues, and it may be a potential predictive marker for prognosis in patients with ovarian cancer.

Introduction

Ovarian cancer is the fifth leading cause of cancer-related deaths in women. According to the GLOBOCAN 2012 database, the incidences of ovarian cancer are 9.1 per 1,00,100 in developed countries and 5.0 per 1,00,000 in developing countries.1 There-into, approximately 70% is high-grade serous carcinomas.2 Up to now, despite the effective treatments including radical resection, systemic chemotherapy, and targeted drugs for patients, the average 5-year survival is still only at 46%.3 Ovarian cancer is a multifactorial disease caused by the interaction of genetic and epigenetic factors.4,5 (TSGs). Hypermethylation in the proximal promoter region often contributes to the transcriptional downregulation but methylation in exons is associated with active transcription.6,7 Recently, mounting evidences demonstrated that DNA methylation was involved in ovarian cancer.8–10 Therefore, identifying the role of TSG methylation in patients with ovarian cancer is of value.

P16 (also known as CDKN2A), a classical TSG, is located on chromosome 9p21 and plays an important role in cell cycle regulation by decelerating cells progression from G1 to S phase.11,12 It has become clear that the expression of P16 is reduced by DNA methylation.13–15 Also, P16 inactivation upregulates retinoblastoma (RB) protein by stimulating the cyclin-dependent kinases (CDKs) and RB pathway, which leads to dysfunction of cell proliferation and apoptosis, thereby further facilitating carcinogenesis.16 Indeed, several types of cancer, including ovarian cancer, exhibit a methylation phenotype of P16.17–19

To date, even though abundant studies have been conducted to explore the role of P16 promoter methylation in ovarian cancer, the results are still inconclusive. Several studies reported that P16 promoter methylation was associated with an increasing trend in ovarian cancer,20–23 while, other studies suggested that P16 promoter methylation was not related to the occurrence of ovarian cancer.24–30 Interestingly, even the conclusions in two published meta-analyses were inconsistent. Xiao et al reported that aberrant methylation of P16 was significantly associated with ovarian carcinogenesis,31 while Jiang et al suggested no association between P16 methylation and epithelial ovarian cancer.32

Considering these conflicting conclusions on the role of methylated P16 in ovarian cancer, we performed an adaptive synthesized analysis to quantitatively evaluate the occurrence frequency, clinicopathological features, and potential prognostic significance of P16 promoter methylation in ovarian cancer. Moreover, we searched The Cancer Genome Atlas (TCGA) database, collecting hundreds of ovarian cancer samples with whole genome DNA methylation datasets to validate our meta-analysis.

Materials and methods

Search strategy and selection criteria

PubMed, Embase, Web of Science, and China National Knowledge Infrastructure were searched up to April 12, 2017, by the following keywords and search items: (P16 OR P16 OR CDKN2A) AND (methylation OR hypermethylation OR demethylation) AND (ovarian OR ovary) AND (cancer OR carcinoma OR neoplasm). The search was limited to human studies, without language restriction. Moreover, a manual search of the relevant references was implemented to identify the potentially additional articles.

The following criteria were used for screening eligible studies: 1) case–control studies evaluating the association between P16 promoter methylation and ovarian cancer risk, or case only studies evaluating the association of P16 promoter methylation with clinicopathological features or prognosis in ovarian cancer; 2) articles providing sufficient information for calculating an odds ratio (OR) and corresponding 95% CI, or study offering hazard ratio (HR) and 95% CI directly; 3) sample types limited to tissues; and 4) studies with full-text articles. It is worth noting that when multiple reports were published from a same study population, only the most recent or complete information was included in this meta-analysis. Meanwhile, studies with Newcastle Ottawa Scale (NOS) scores greater than or equal to five were enrolled.

Data extraction and quality assessment

With a preformed unified form, data were extracted independently by two investigators, and disagreements were resolved by discussion till consensus was achieved. The following information was extracted from studies: the first author’s name, publication year, country, geographical location, sample size, age of patients in the case group, the frequencies of methylation in the case and control groups, methods for detecting methylation, methylation site, disease stage, tumor grade, histological subtype, and effects on survival outcomes.

The quality of eligible case–control studies was assessed according to the NOS criteria.33 The NOS criteria are based on three aspects: 1) subject selection: 0–4; 2) comparability of subject: 0–2; 3) clinical outcome: 0–3.

Statistical analysis

Statistical analysis was conducted with Review Manager 5.2 (Cochrane Collaboration, Oxford, UK) and the Stata 12.0 (Stata Corporation, College Station, TX, USA). ORs with corresponding 95% CIs were calculated to estimate the association between P16 promoter methylation and ovarian cancer risk or clinicopathological features. Meanwhile, HRs and 95% CIs were used to assess the prognosis of P16 promoter methylation on ovarian cancer. Inter-study heterogeneity was estimated with the Cochran’s Q statistic and I2 tests. P<0.05 or I2>50% indicated substantial heterogeneity, and then the random-effects model was applied. Otherwise, the fixed-effects model was selected. We also explored sources of heterogeneity using meta-regression and subgroup analyses by publication year, geographical location, method, and case sample size. Additionally, sensitivity analysis was performed to investigate the influence of individual study. Publication bias was evaluated by funnel plots and Begg’s test, and P<0.05 was considered statistically significant. It is worth mentioning that, for some trials containing no events in both case and control arms, as no information supplied about the likely magnitude of the effect, we excluded such trials when synthesizing data.34

TCGA datasets extraction and analysis

We collected DNA methylation datasets of 582 ovarian cancer cases and 12 ovarian normal tissues from TCGA (“TCGA-ovary [OV]” project) program.35 The methylation measurement was performed using Illumina HumanMethylation27 BeadChip. Beta value of each CpG site was extracted to assess the methylation level of CDKN2A gene. Beta value was calculated based on the intensities of the methylated (M) and unmethylated (U) bead types: beta value = M/(M+U).36 The difference of DNA methylation level of CpG sites between ovarian tumor tissues and normal ovarian tissues in TCGA database was analyzed by Student’s t-test on the means. P16 gene expression value (fragments per kilobase of transcript per million mapped reads) in ovarian tumor tissues (TCGA, “TCGA-OV” project) was also extracted. Pearson’s product-moment correlation between P16 gene expression levels and methylation of its CpG islands was evaluated. Data analysis was performed using R software (R i386 3.4.0). P-values were adjusted via Bonferroni correction.

Results

Identification of relevant studies

The procedure of study selection is outlined in Figure 1. We identified 233 articles in the initial literature search. A total of 153 references remained after removing duplicates. After reading titles and abstracts, 84 records were identified for further full-text assessment, which further excluded 60 more articles. Finally, 24 studies from 1997 to 2015 were included in this meta-analysis.17,20,22–30,37–49

Figure 1

Flow diagram of study selection.

Baseline characteristics of included studies

Out of the 24 studies, 11 studies were conducted in Asia, 7 in Europe, 4 in America, 1 in Africa, and 1 in Oceania. The detection methods of methylation in 20 studies were methylation-specific PCR (MSP) and real-time quantitative MSP, while methylation-specific multiplex ligation-dependent probe amplification was used in two studies, MethyLight was used in one study, and Southern analysis was used in one study. Among the 24 articles, 20 studies17,20,22–30,37–40,42,45–47,49 addressed the risk of P16 promoter methylation in ovarian cancer, 10 studies20,25,28,29,38,41,43,44,47,48 covered clinicopathological features, and 3 studies20,42,43 discussed prognosis. To explore the relationship between P16 promoter methylation and ovarian cancer risk, three groups, that is, normal tissues, benign tissues, and low malignant potential or borderline tumor tissues (LMP), were compared. The NOS scores of all case–control studies were ≥5. The basic characteristics of all included studies are summarized in Tables 1 and 2.

Table 1

Characteristics of studies included for the association between P16 methylation and ovarian cancer risk

Authors	Year	Country	Geographical location	Sample sizea	Case number				Age (years)d	Sample type	Method	Methylation site	NOS score
					C (M/n)	LMP (M/n)	B (M/n)	NT (M/n)
Moselhy et al17	2015	Saudi Arabia	Asia	Small	14/18	NA	12/32	NA	52.3±12.1	FFPET	MSP	Promoter	7
Bhagat et al20	2014	India	Asia	Large	58/134	5/23	11/26	0/15	49.55±9.72	FFT	qMSP	Promoter	7
Ozdemir et al24	2012	Turkeyb	Asia	Large	1/75	NA	NA	0/75	NA	Tissue	MS-MLPA	Promoter	7
Ho et al37	2012	Taiwan	Asia	Small	1/47	NA	6/29	NA	50(32–66)	FFT	MS-MLPA	Promoter	7
Cuľbová et al38	2011	Slovakia	Europe	Small	5/13	0/2	5/19	NA	54.8 (34–74)	FFT	MSP	Promoter	6
Abou-Zeid et al22	2011	Egyptc	Africa	Large	21/52	NA	9/43	4/40	60(49–74)	FFT	qMSP	Promoter	7
Gu et al39	2009	China	Asia	Large	8/87	NA	13/42	NA	51(21–69)	Tissue	MethyLight	Promoter	7
Shen et al25	2008	China	Asia	Large	13/63	NA	NA	0/30	52.8 (33–76)	FFT	MSP	Promoter	6
Wu et al40	2007	Norway	Europe	Large	0/52	0/2	0/2	NA	NA	FFT	MSP	Promoter	6
Tam et al26	2007	HongKong	Asia	Large	17/89	1/16	1/19	4/16	53.1±1.4	FFT	MSP	Promoter	7
Wiley et al42	2006	Italy	Europe	Large	89/215	4/19	NA	NA	57.7±11.4	FFT	MSP	Promoter	7
Li et al27	2006	China	Asia	Small	6/18	NA	NA	0/10	NA	Tissue	MSP	Promoter	5
Makarla et al29	2005	USA	America	Small	7/23	5/23	3/23	0/16	51.5 (20–86)	FFT	MSP	Promoter	7
Liu et al28	2005	USA	America	Large	13/52	NA	NA	15/40	61.5±9.4	FFT	MSP	Promoter	5
Dhillon et al23	2004	India	Asia	Small	10/25	NA	NA	1/75	NA	Tissue	MSP	Promoter	7
Rathi et al30	2002	USA	America	Small	5/49	NA	NA	0/16	56(40–79)	FFT	MSP	Promoter	7
Strathdee	2001	UK	Europe	Large	0/93	NA	NA	0/18	NA	FFT	MSP	Promoter	6
et al46
Brown et al45	2001	UK	Europe	Small	0/30	0/13	0/14	NA	NA	FFT	MSP	Promoter	5
McCluskey et al47	1999	USA	America	Small	21/37	11/15	14/20	NA	NA	FFT	MSP	Promoter	6
Shih et al49	1997	Australia	Oceania	Small	0/45	0/3	0/2	NA	NA	Tissue	Southern analysis	Promoter	5

Notes:

We defined n<50 as small size and ≥50 as large size.

Turkey is a transcontinental Eurasian country and is usually assigned to Asia internationally.

Egypt is a transcontinental country spanning the northeast corner of Africa and southwest corner of Asia, usually assigned to Africa internationally.

Age data are presented as mean ± SD or median (IQR).

Abbreviations: B, benign tissues; BL, borderline; C, cancer tissues; FFPET, formalin fixed and paraffin embedded tissues; FFT, fast frozen tissues; LMP, low malignant potential or borderline tumor tissues; M, methylated; MS-MLPA, methylation-specific multiplex ligation-dependent probe amplification; MSP, methylation-specific PCR; n, number of patients in the group; NA, not available; NT, normal tissues; NOS, Newcastle Ottawa Scale; qMSP, real-time quantitative MSP.

Table 2

Characteristics of studies included for the association between P16 methylation and clinicopathological features of ovarian cancer

Authors	Year	Country	Geographical location	Number of patients	Age (years)a	Tumor stage		Tumor grade		Histological subtype
						I–II (M/n)	III–IV (M/n)	1–2 (M/n)	3 (M/n)	Serous (M/n)	Non-serous (M/n)
Bhagat et al20	2014	India	Asia	134	49.55±9.72	19/41	39/93	18/45	40/89	32/76	26/58
Cuľbová et al38	2011	Slovakia	Europe	13	54.8 (34–74)	NA	NA	NA	NA	2/6	3/7
Shen et al25	2008	China	Asia	63	52.8 (33–76)	4/22	9/41	6/36	7/27	7/34	6/29
Yang et al41	2006	Hong Kong	Asia	49	48.8 (26–79)	4/24	5/25	6/22	3/25	3/17	6/32
Makarla et al29	2005	USA	America	23	51.5 (20–86)	NA	NA	NA	NA	2/9	5/14
Liu et al28	2005	USA	America	52	61.5±9.4	NA	NA	10/41	3/11	NA	NA
Katsaros et al43	2004	Italy	Europe	249	57(19–82)	22/68	68/152	26/75	64/141	40/86	50/141
Hashiguchi et al44	2001	Japan	Asia	46	NA	4/21	2/20	7/33	0/13	2/14	5/32
McCluskey et al47	1999	USA	America	29	NA	NA	NA	NA	NA	1/14	1/15
Milde-Langosch et al48	1998	Germany	Europe	44	NA	NA	NA	NA	NA	3/11	13/33

Note:

Age data are presented as mean ± SD or median (IQR).

Abbreviations: M, methylated; n, number of patients in the group; NA, not available.

Quantitative data synthesis

Association between P16INK4a promoter methylation and ovarian cancer risk

A total of 1,217 ovarian cancers, 116 LMP cancers, 271 benign patients, and 351 normal controls were quantitatively synthesized in this analysis. Results indicated that the frequency of P16 promoter methylation in cancer tissues was significantly elevated than that in normal tissues (OR=5.01, 95% CI=1.55–16.14) and LMP tissues (OR =1.88, 95% CI=1.10–3.19), but similar to benign tissues (OR =1.18, 95% CI=0.52–2.65; Figure 2). Further analyses showed that the frequencies of P16 promoter methylation in benign tissues and LMP tissues were not higher than those in normal tissues (OR =2.28, 95% CI=0.37–14.09; OR =2.28, 95%CI=0.15–34.73, respectively; Figure 3).

Figure 2

Forest plots for the association between P16 methylation and ovarian cancer risk.

Notes: (A) Cancer tissues vs normal tissues; (B) cancer tissues vs benign tissues; (C) cancer tissues vs LMP tissues.

Abbreviations: LMP, low malignant potential or borderline tumor tissues; M–H, Mantel–Haenszel.

Figure 3

Forest plots for the association between P16 methylation and ovarian diseases.

Notes: (A) Benign tissues vs normal tissues; (B) LMP tissues vs normal tissues.

Abbreviations: LMP, low malignant potential or borderline tumor tissues; M–H, Mantel–Haenszel.

With large heterogeneity, meta-regression and subgroup analyses were conducted by the publication year, geographical location, method, and case sample size in the comparison of cancer tissues vs normal tissues. Meta-regression found that case sample size was significantly correlated with the inter-study heterogeneity (P=0.041) while other covariates were not (Table 3). Furthermore, as shown in Table 3, subgroup analyses revealed that the OR was 5.69 (95% CI=0.42–76.14) for the publication year ≤2005 and 4.71 (95% CI=1.30–17.07) for >2005 under the random-effects model. For geographical location, the OR was 7.85 (95% CI=1.33–46.32) in Asia, 2.31 (95% CI=0.24–22.01) in America, and 6.10 (95% CI=1.89–19.69) in Africa under random-effects model. For test method, the OR for MSP was 4.49 (95% CI=0.97–20.64) under random-effects model and 8.11 (95% CI=2.93–22.40) for other methods under fixed-effects model. In addition, the OR was 15.75 (95% CI=4.05–61.34) for sample size <50 in fixed-effects model and 2.21 (95% CI=1.33–3.67) for that ≥50 in random-effects model.

Table 3

Meta-regression and subgroup analyses of P16 methylation in comparison of cancer tissues vs normal tissues

Stratified analysis	Number of studies	Pooled OR (95% CI)		Meta-regression	Heterogeneity
		Random	Fixed	P-value	I2 (%)	P-value
Publication year				0.376
≤2005	4	5.69 (0.42–76.14)	2.17 (1.17–4.05)		84	0.0003
>2005	6	4.71 (1.30–17.07)	4.65 (2.32–9.30)		56	0.05
Geographical location				0.161
Asia	6	7.85 (1.33–46.32)	5.87 (2.70–12.78)		70	0.005
America	3	2.31 (0.24–22.01)	1.15 (0.56–2.37)		68	0.05
Africa	1	6.10 (1.89–19.69)	6.10 (1.89–19.69)		–	–
Method				0.651
MSP	7	4.49 (0.97–20.64)	2.33 (1.38–3.92)		77	0.0003
Others	3	6.79 (2.43–18.94)	8.11 (2.93–22.40)		0	0.57
Case sample size				0.041
<50	4	17.21 (4.54–65.28)	15.75 (4.05–61.34)		0	0.58
≥50	6	2.21 (1.33–3.67)	2.74 (0.71–10.53)		75	0.001

Abbreviations: MSP, methylation-specific PCR; OR, odds ratio.

Association between P16 promoter methylation and clinicopathological features in patients with ovarian cancer

Ten studies comprising 680 samples were enrolled to assess whether or not the abnormal P16 promoter methylation was associated with ovarian cancer clinicopathological characteristics. As displayed in Figure 4, no statistically significant correlation was found between P16 promoter methylation and age of patients (≥60 vs<60: OR =1.39, 95% CI=0.66–2.92), clinical stage (III–IV vs I–II: OR =1.21, 95% CI=0.81–1.82), grade (3 vs 1–2: OR=1.20, 95% CI=0.82–1.1.75) as well as histological subtype (serous vs non-serous: OR=1.09, 95% CI=0.76–1.55).

Figure 4

Forest plots for the association between P16 methylation and clinicopathological features in ovarian cancer.

Notes: (A) Age; (B) clinical stage; (C) tumor grade; (D) histological subtype.

Abbreviation: M–H, Mantel–Haenszel.

Prognostic value of P16 promoter methylation in patients with ovarian cancer

Only two studies42,43 containing 464 patients evaluated the P16 promoter methylation on progression-free survival (PFS) and three studies20,42,43 containing 600 patients on overall survival (OS). The combined results revealed P16 promoter methylation was significantly associated with a poor PFS by univariate Cox proportional hazards regression model (HR=1.68, 95% CI=1.26–2.24; Figure 5A). After considering potential confounders by adjusting for age at diagnosis or surgery, disease stage, histological grade, and residual tumor size, the pooled HR was 1.55 (1.15–2.08; Figure 5B). Survival analysis also showed that P16 promoter methylation reduced OS in univariate and multivariate Cox regression models (HR =1.28, 95% CI=0.97–1.68; HR =1.16, 95% CI=0.87–1.55, respectively; Figure 5C and D), but the differences were not statistically significant.

Figure 5

Forest plots for P16 methylation on survival analysis in univariate and multivariate Cox regression model.

Notes: (A) PFS in univariate Cox regression model; (B) PFS in multivariate Cox regression model; (C) OS in univariate Cox regression model; (D) OS in multivariate Cox regression model.

Abbreviations: OS, overall survival; PFS, progression-free survival; SE, standard error.

Sensitivity analysis and publication bias

As presented in Figure 6A–C, no single study significantly affected the pooled ORs in the sensitivity analysis, indicating our analysis was relatively stable and credible. Funnel plots and Begg’s test were used to evaluate the publication bias. The funnel plots were largely symmetric suggesting there were no publication biases in the meta-analysis of P16 promoter methylation and ovarian cancer risk, which was confirmed by the Begg’s test (Figure 6D–F).

Figure 6

Sensitivity analyses and Begg’s test for publication bias of P16 methylation during the carcinogenesis of ovarian cancer.

Notes: (A and D) Cancer tissues vs normal tissues; (B and E) sensitivity analysis for the comparison of cancer tissues vs benign tissues; (C and F) sensitivity analysis for the comparison of cancer tissues vs LMP tissues.

Abbreviations: LMP, low malignant potential or borderline tumor tissues; SE, standard error.

Methylation level of P16 measured by TCGA program

To further explore the methylation level of P16 in ovarian tumor tissues, we extracted DNA methylation data of P16 CpG sites measured with Illumina HumanMethylation27 BeadChip from TCGA program. As shown in Table 4, the beta values of 582 ovarian tumor tissues and 12 normal ovarian tissues were extracted for analysis. Obviously, the methylation levels of seven out of nine CpG sites were significantly increased in the ovarian tumor tissues compared with the normal tissues (cg03079681, cg07752420, cg09099744, cg10895543, cg11653709, cg12840719, and cg26673943). Among these regions, methylation level of probe cg26673943 region (located at the promoter region of P16) was negatively associated with P16 expression in ovarian cancer patients (adjusted P-value <0.000001). However, methylation levels of the rest six probes, which are located at non-promoter region tended to be positively associated with P16 gene expression. Additionally, we found that methylation level of probe cg13479669 region was lower in tumor tissues compared with normal tissues, and negatively associated with P16 gene expression in tumor tissues. These results suggest that hypermethylation of P16 might be correlated with ovarian carcinogenesis and development. Nevertheless, it seems that the methylation at promoter region or non-promoter region has contrary effects on P16 gene expression.

Table 4

Methylation of P16 CpG sites on Illumina HumanMethylation 27 BeadChip from TCGA datasets

Probe (Illumina HumanMethylation 27)	CpG island location (chromosome: DNA range)	Normal tissue beta value (mean, n=12)	Tumor tissue beta value (mean, n=582)	Adjusted P-valuea	Pearson correlation coefficient	Adjusted P-valueb
cg00718440	9: 21983444–21986348	0.016	0.016	0.960249	0.194104	0.001719
cg03079681	9: 21983444–21986348	0.015	0.026	<0.000001	0.012972	1.0
cg07752420	9: 21958106–21958899	0.149	0.653	<0.000001	0.569887	<0.000001
cg09099744	9: 21958106–21958899	0.099	0.642	<0.000001	0.630768	<0.000001
cg10895543	9: 21958106–21958899	0.120	0.651	<0.000001	0.624147	<0.000001
cg11653709	9: 21958106–21958899	0.144	0.610	<0.000001	0.555400	<0.000001
cg12840719	9: 21958106–21958899	0.092	0.594	<0.000001	0.627484	<0.000001
cg13479669	9: 21983444–21986348	0.045	0.027	0.004226	–0.150891	0.0333435
cg26673943	9: 21983444–21986348	0.047	0.056	0.042428	–0.269361	<0.000001

Notes:

P-value of t-test of the difference between normal tissue beta value and tumor tissue beta value.

P-value of Pearson’s correlation between the tumor tissues beta value and CDKN2A expression (n=368).

Abbreviation: TCGA, The Cancer Genome Atlas.

Discussion

Ovarian cancer is one of the leading causes of cancer-related deaths in women.50 Identification of early disease indicators for diagnosis and prognosis is of clinical value. P16, which resembles classic TSGs such as P53, is an important negative regulator of cell growth and proliferation.16 It has been synthetically evaluated for aberrant P16 methylation in numerous cancers,51–54 including ovarian cancer.31,32 Considering the conflicting conclusions in two meta-analyses and the lack of comprehensive assessment on the role of methylated P16 in ovarian cancer, we performed an adaptive synthesized analysis to investigate the relationships between P16 promoter methylation and ovarian cancer risk, as well as clinicopathological features and prognostic value in ovarian cancer. Meanwhile, we searched TCGA data to validate our meta-analysis.

Our meta-analysis demonstrated that P16 promoter methylation in cancer tissues was significantly higher than that in normal tissues (P<0.05), but not much increased than that in benign tissues. Compared with normal tissues, the frequency of P16 promoter methylation was 2.28-fold higher in both benign tissues and LMP tissues (P>0.05), but the differences were not statistically significant. The reason for this phenomenon may be that the transformation of normal cells to cancer cells is a long-term, gradual, and multiphase process.55 Although not establishing a strong correlation between P16 promoter methylation and cancer progression, the above results do suggest a possibility that epigenetic alteration of P16 promoter methylation might play a certain role in ovarian carcinogenesis and might be useful in distinguishing malignant tumor from healthy ovarian tissues. Considering the evident heterogeneity, we conducted subgroup analyses based on probable covariates in the comparison of cancer tissues vs normal tissues. For geographical location, P16 promoter methylation is a risk factor in Asia and Africa, but not in America. The divergence may be underscored in a large part to a combination of differences in allele frequencies and complex epistasis or gene–environment interactions.56 A review also outlined that some factors such as distinct physical appearance, behavior, and response to environ mental agents and drugs between human populations could have contributed to the epigenetic variations.57 Similar findings appeared in the subgroup analyses of different methods and publication year. Kurdyukov and Bullock58 suggested that it was essential to choose an appropriate method in a suitable region to answer a particular biological question in studies of DNA methylation. Additionally, the 95% CI was large in the group of small sample size while relatively small in the group of large sample size, implying the conclusion may not be reliable unless studies should be conducted using a sufficient number of samples. Previous studies also demonstrated that the methylation status in blood samples or fluids might be different from that in tissues.59,60 Thus, our results should be interpreted with caution because sample types were limited to tissues in studies included in this meta-analysis.

Previous studies indicated that P16 promoter methylation was associated with poorly differentiated tumors and was different in histological subtype in ovarian cancer.22,43 However, we could not establish any significant correlations between P16 promoter methylation and clinicopathological features, including age, clinical stage, tumor differentiation or histological subtype in this study. Therefore, it might not be essential to predict the invasion and metastasis of ovarian cancer.

Katsaros et al43 and Wiley et al42 reported association of P16 promoter methylation with PFS and OS in ovarian cancer, while Bhagat et al20 found no significant value in predicting prognosis. In the present study, we discovered that P16 promoter methylation represented a risk factor for PFS. For OS, patients with P16 promoter methylation also had a slightly elevated risk, though the differences are not statistically significant. This trend was also observed in other types of cancer.51,54 However, its statistical confirmation requires large studies. The data from TCGA also indicated that methylation level of probe cg26673943 region (located at the promoter region of P16) in the ovarian tumor tissues was higher than normal ovarian tissues. Increased methylation of CpG island at the promoter region was negatively associated with P16 gene expression, while methylation of CpG islands at non-promoter regions was positively associated with P16 expression.

Compared with previous meta-analyses,31,32 our meta-analysis had several improvements. First, the development of ovarian cancer is a multistep procedure involving normal tissues, benign disease, LMP or borderline tumor, and malignant tumor.20 We compared malignant ovarian cancer with LMP tumors, benign disease, and normal samples to give more rigorously to the analysis. Second, with 1,217 malignant ovarian cancer patients, 116 LMP, 271 benign patients, and 351 normal samples, the sample size in our study is much larger than that of all previous meta-analyses. Finally, we included the clinicopathological features and prognostic significance of P16 promoter methylation in ovarian cancer for more comprehensive understanding of the underlying pathogenesis of ovarian cancer. These strengths make our study a useful effort in seeking better understanding of the P16 promoter methylation in ovarian cancer.

Limitations

Several potential limitations in our current study should be noted. First, the heterogeneity was still large after subgroup analyses in the assessment of the association between P16 promoter methylation and ovarian cancer risk, which may affect the statistical power. Second, as a retrospective study, a potential unidentified confounding information and selection bias may exist in our meta-analysis. We could not eliminate the possibility of publication bias, where positive results are likely published than negative results. Third, the total sample size was still relatively small for reliably assessing the prognostic value of P16 promoter methylation in ovarian cancer. Fourth, none of the studies included in our meta-analysis defined the region considered as promoter or provided specific methylation sites. Therefore, we are unable to establish whether or not they focused on the same sequence of P16 gene. However, the impact of methylation on transcriptional potential depends on the density of the methylated CpG islands and their location relative to the transcription start site. This highlights the importance of a uniform and full-scale reporting of study designs and outcomes. Additionally, previous researches showed that the occurrence of P16 promoter methylation may depend on the histological subtype.41,48,61 However, we are unable to extract sufficient data to analyze the association between P16 promoter methylation and high-grade serous carcinomas because no detailed information of P16 promoter methylation in high-grade serous carcinomas was provided in the eligible articles.

Although with certain limitations, our study is a comprehensive meta-analysis focusing on the correlation of aberrant P16 promoter methylation with the initiation, development, and prognosis of ovarian cancer to provide a new insight into the pathogenesis of ovarian cancer.

Conclusion

In conclusion, our meta-analysis suggests that aberrant methylation of P16 promoter may be essential to the initiation of ovarian cancer and in distinguishing malignant from healthy ovarian tissues. Besides, P16 promoter methylation is a potential predictive factor for poor prognosis in ovarian cancer. This study indicates the need for multicenter large-scale studies to confirm the role of P16 promoter methylation in ovarian cancer.