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Erschienen in: World Journal of Surgical Oncology 1/2018

Open Access 01.12.2018 | Review

Positive surgical margin is associated with biochemical recurrence risk following radical prostatectomy: a meta-analysis from high-quality retrospective cohort studies

verfasst von: Lijin Zhang, Bin Wu, Zhenlei Zha, Hu Zhao, Yuefang Jiang, Jun Yuan

Erschienen in: World Journal of Surgical Oncology | Ausgabe 1/2018

Abstract

Background and purpose

Although numerous studies have shown that positive surgical margin (PSM) is linked to biochemical recurrence (BCR) in prostate cancer (PCa), the research results have been inconsistent. This study aimed to explore the association between PSM and BCR in patients with PCa following radical prostatectomy (RP).

Materials and methods

In accordance with the guidelines of the Preferred Reporting Items for Systematic Reviews and Meta-Analyses (PRISMA), PubMed, EMBASE and Wan Fang databases were searched for eligible studies from inception to November 2017. The Newcastle–Ottawa Scale was used to assess the risk of bias of the included studies. Meta-analysis was performed by using Stata 12.0. Combined hazard ratios (HRs) and their corresponding 95% confidence intervals (CIs) were calculated using random-effects or fixed-effects models.

Results

Ultimately, 41 retrospective cohort studies of high quality that met the eligibility criteria, comprising 37,928 patients (94–3294 per study), were included in this meta-analysis. The results showed that PSM was associated with higher BCR risk in both univariate analysis (pooled HR = 1.56; 95% CI 1.46, 1.66; p < 0.001) and multivariate analysis (pooled HR = 1.35; 95% CI 1.27, 1.43; p < 0.001). Moreover, no potential publication bias was observed among the included studies in univariate analysis (p-Begg = 0.971) and multivariate analysis (p-Begg = 0.401).

Conclusions

Our meta-analysis demonstrated that PSM is associated with a higher risk of BCR in PCa following RP and could serve as an independent prognostic factor in patients with PCa.
Hinweise

Electronic supplementary material

The online version of this article (https://​doi.​org/​10.​1186/​s12957-018-1433-3) contains supplementary material, which is available to authorized users.
Zhenlei Zha, Hu Zhao and Yuefang Jiang contributed equally to this work.

Background

Prostate cancer (PCa) is the most diagnosed malignancy and the second leading cause of cancer-related deaths among men in Western countries [1]. Radical prostatectomy (RP) has been shown to have a cancer-specific survival benefit for men with clinically localised PCa [2]. Although many patients are disease-free after surgery, nearly 30% [3] of patients still continue to experience biochemical recurrence (BCR). Defined as a detectable prostate-specific antigen (PSA) level following RP in the absence of clinical progression, BCR is the most common pattern of disease relapse [4]. Patients with BCR have a considerably worse prognosis, often develop metastasis, and can die of the disease [3, 4]. Therefore, identifying prognostic predictors of BCR after RP to assist clinicians in predicting outcomes for decision making is required.
Numerous nomograms including pathological tumour stage [5], Gleason’s score [6], seminal vesicle invasion [7], and lymphatic invasion [8] have been developed to predict subsequent risk of BCR after RP. Unfortunately, because the collective prognostic value of these factors is unsatisfactory, better biomarkers are urgently needed. Positive surgical margin (PSM) is defined as the histological presence of cancer cells at the inked margin on the RP specimen [9]. Although PSM is frequently reported in radical prostatectomy series, their clinical relevance remains uncertain despite extensive investigation. A number of studies have demonstrated an association between PSM and BCR [5, 10, 11], while others have observed insignificant or even contrary correlations [1214].
Previously, Yossepowitch [15] systematically reviewed related studies on PSM reporting survival of surgical treatment for patients with PCa. These studies suggested that PSM in PCa should be considered an adverse oncological outcome. Nevertheless, a meta-analysis was not performed because of low-quality evidence and potential risks of bias. A meta-analysis utilises statistical methods to contrast and combine results from multiple studies, increasing the statistical power and reproducibility compared with individual studies [16]. Hence, to obtain the most conclusive results, we conducted a meta-analysis with high-quality retrospective cohort studies to assess the prognostic value of PSM in BCR.

Methods

This meta-analysis was conducted in accordance with the Preferred Reporting Items for Systematic Reviews and Meta-Analyses (PRISMA) guidelines. A comprehensive search of the literature in PubMed, EMBASE, and Wan Fang databases up to November 2017 was performed using a combined text and MeSH heading search strategy with the following terms: (“prostate cancer” or “prostate AND neoplasms”) and (“radical prostatectomy”) and (“positive surgical margin”) and (“biochemical recurrence” OR “biochemical failure”). In addition, reference lists in the recent reviews, meta-analysis, and included articles were manually searched to identify related articles. The language of the publications was limited to English and Chinese.

Inclusion and exclusion criteria

We defined the inclusion and exclusion criteria for study selection at the initiation of the search. The following inclusion criteria were used: (1) included definitive diagnosis of PCa and PSM assessed by pathologists; (2) all patients underwent RP treatment; (3) BCR after RP was defined; (4) the risk of BCR was estimated as hazard ratios (HRs) with corresponding 95% confidence intervals (CIs) or the risk could be calculated from the reported data; and (5) published in English or Chinese. The following exclusion criteria were used: (1) letters, reviews, case reports, editorials, and author responses; (2) non-human studies; (3) studies that did not analyse the outcome after PSM and BCR; (4) studies with duplicated patient populations that had been reported in previous publications; or (5) articles contained elements that were inconsistent with the inclusion criteria.

Data extraction and quality assessment

Two investigators (Zhenlei Zha and Hu Zhao) independently extracted the data from all eligible publications. Any differences among evaluators were resolved by discussion with a third investigator (BinWu). The following data were extracted from the included studies using a standardised data collection protocol (Table 1, Table 2): first author’s name, year of publication, country, recruitment period, sample size, patient’s age, preoperative PSA level, Gleason score, pathological stage, positive percentage of PSM and BCR, definition of BCR, follow-up time, and the HRs (95% CIs) of PSM in univariate or multivariate Cox analyses for BCR. The quality of the eligible studies was evaluated according to the Newcastle–Ottawa Scale (NOS), which include three domains (selection of the study population, comparability of the groups, ascertainment of the outcome). We identified articles of “high quality” as those with NOS scores of 6–9, whereas scores of 0–5 were considered to indicate poor quality.
Table 1
Primary characteristics of the included studies
Author
Year
Country
No. of patients
Recruitment period
Age
(years)
p-PSA
(ng/ml)
Follow-up (months)
Surgical approach
Wettstein et al. [35]
2017
Switzerland
371
2008–2015
Median (range)
63 (41–78)
Median (range)
6.79 (0.43–81.4)
Median (range)
28 (1–64)
NA
Xun et al. [6]
2017
China
172
2003–2014
Median (IQR)
68 (62–72)
Median (IQR)
16.1 (10.9–28.3)
Median (IQR)
46.4 (33.4–62.4)
NA
Meyer et al. [36]
2017
Germany
903
1992–2005
Median (IQR)
63 (59–66)
Median (IQR)
6.4 (4.6–9.0)
Median (IQR)
133 (97–157)
NA
Gandaglia et al. [37]
2017
Multi-centred
94
2011–2015
Median (IQR)
64.3 (57.1–68.9)
Median (IQR)
9.7 (5.1–17.5)
Median (IQR)
23.5 (18.7–27.3)
Robot-assisted RP
Shangguan et al. [33]
2016
China
172
2003–2014
Median (range)
68 (62–72)
Median (range)
16.1 (10.9–28.3)
Median (IQR)
46.4 (33.4–62.4)
Open and laparoscopic RP
Zhang et al. [34]
2016
China
168
2006–2011
Median (range)
69 (53–85)
Median (range)
13.31 (4.59–36.12)
Median (range)
68 (7–98)
Laparoscopic RP
Simon et al. [12]
2016
Multi-centres
411
2001–2013
Mean ± SD
61 ± 6.1
NA
Median
63
NA
Sevcenco et al. [38]
2016
Multi-centres
7205
2000–2011
Median (IQR)
61 (57–66)
Median (IQR)
6 (4–9)
Median (IQR)
27 (19–48)
NA
Pagano et al. [20]
2016
USA
180
1990–2011
Median (range)
63.7 (58.8–67.6)
Median (range)
9.1 (6.3–17.1)
Median (range)
26.7 (8.8–66)
NA
Moschini et al. [39]
2016
USA
1011
1987–2012
NA
Median
12.0
Median
211.2
NA
Mortezavi et al. [40]
2016
Switzerland
100
1999–2007
Mean ± SD
63.5 ± 6.5
Mean ± SD
9.6 ± 8.3
Median (range)
126 (60–176)
Laparoscopic RP
Mao et al. [41]
2016
China
106
2008–2009
Mean (range)
68.1 (48–83)
Mean (range)
25.1 (3.1–104.3)
Median (range)
69 (8–84)
Laparoscopic RP
Whalen et al. [29]
2015
USA
609
2005–2011
Mean ± SD
61.2 ± 7.3
Mean ± SD
6.8 ± 6.3
Median (range)
20.5 (1–80)
NA
Song et al. [42]
2015
Korea
2137
1988–2011
Median (IQR)
67 (63–71)
Median (IQR)
6.9 (4.7–11.2)
Mean (range)
39.4 (8–1834)
NA
Reeves et al. [43]
2015
Australia
1479
2005–2012
Median
62
NA
Median
14
NA
Hashimoto et al. [5]
2015
Japan
837
2006–2013
Median (range)
65 (39–78)
Median (range)
6.9 (3–47.4)
Median (range)
20.5 (1.3–91.3)
Robot-assisted RP
Alvin et al. [44]
2015
Singapore
725
2003–2013
Median (range)
62 (37–79)
Median (range)
7.9 (0.79–72.9)
Mean (range)
28.5 (6–116)
Robot-assisted RP
Touijer et al. [13]
2014
USA
369
1988–2010
Median (IQR)
62 (57–66)
Median (IQR)
8 (5–15)
Median
48
NA
Ritch et al. [45]
2014
USA
979
2003–2009
Median
62
NA
Median
47
Open and robot-assisted RP
Kang et al. [21]
2014
Korea
3034
2004–2011
Mean ± SD
65.9 ± 6.6
Mean ± SD
11.6 ± 12.2
Median
47
NA
Fairey et al. [14]
2014
USA
229
1987–2008
Median (range)
65 (41–83)
NA
Median (range)
174 (2.4–253.2)
NA
Turker et al. [46]
2013
Turkey
331
1993–2009
Mean ± SD
62.79 ± 6.4
Mean ± SD
11.1 ± 10.5
Mean ± SD
29.7 ± 33.2
NA
Sammon et al. [10]
2013
USA
794
1993–2010
Mean ± SD
63.4 ± 8.1
Mean ± SD
5.6 ± 3.6
Median (IQR)
26.4(12.2–54.6)
NA
Chen et al. [30]
2013
China
152
2004–2011
NA
NA
Median (range)
48 (12–87)
Laparoscopic RP
Sooriakumaran et al. [11]
2012
Sweden
944
2002–2006
Median (IQR)
62.2 (58.2–65.8)
Median (IQR)
6.4(4.8–9.0)
Median (IQR)
75.6(67.2–86.4)
Robot-assisted RP
Lu et al. [31]
2012
China
894
1993–1999
Median (IQR)
62 (57–66)
Median (IQR)
6.0 (4.5–8.6)
Median (IQR)
9.9 (6.1–11.3)
NA
Iremashvili et al. [47]
2012
USA
1444
2003–2010
Mean (range)
61.3 (56–66.3)
Mean (range)
5.7 (4.5–8.0)
Median (range)
43.2 (3–216)
Open and robot-assisted RP
Connolly et al. [48]
2012
Australia
160
1988–1997
Mean ± SD
63.1 ± 6.3
Median (IQR)
9.95 (6.0–21.4)
Median (IQR)
26.2 (5.5–37.3)
Robot-assisted RP
Busch et al. [49]
2012
Germany
1845
1999–2007
Mean ± SD
62.0 ± 5.9
Median (range)
26.3 (17.0–42.1)
Median (range)
56 (0–35)
Laparoscopic RP
Berge et al. [50]
2012
Norway
577
2002–2008
Mean (range)
61.5 (42–76)
Mean (range)
8.4 (0.3–31)
Median (range)
36 (3–72)
Laparoscopic RP
Lee et al. [51]
2011
Korea
1000
2003–2009
Median (range)
66 (37–82)
Median (range)
7.8 (0.1–261.8)
Mean
39.4
NA
Alenda et al. [23]
2011
France
1248
1998–2008
Mean (range)
63 (44–78)
Mean (range)
10.9 (0.9–134)
Median
23.4
NA
Fukuhara et al. [52]
2010
Japan
364
2000–2009
Median (range)
66 (52–78)
Median (range)
8.1 (1.7–77.7)
Median (range)
33 (10–109)
NA
Cho et al. [53]
2010
Korea
171
2005–2009
Mean (range)
64.4 (49–80)
NA
Mean (range)
23.3 (2–51)
NA
Alkhateeb et al. [26]
2010
Canada
1268
1992–2008
Mean ± SD
62.0 ± 6.6
Median (range)
6.2 (0.1–65.9)
Mean (range)
78.1 (3–192)
NA
Jeon et al. [54]
2009
Korea
237
1995–2004
Mean (range)
64.5 (44–86)
Mean (range)
11.5 (0.2–98)
Median (range)
21.6 (2–88)
NA
Schroeck et al. [55]
2008
USA
3194
1988–2007
Median (IQR)
62.6(57.2–67.9)
Median (IQR)
6.3(4.5–9.6)
Median
31.2
NA
Pavlovich et al. [56]
2008
USA
508
2001–2005
Mean ± SD
57.6 ± 6.7
Mean (range)
6.0 (0.3–27)
Median (range)
12 (2–52)
Laparoscopic RP
Hong et al. [57]
2008
Korea
372
2003–2007
Mean (range)
64.2 (37–72)
Mean (range)
8.7 (0.2–104.2)
NA
NA
Cheng et al. [8]
2005
Indiana
504
1990–1998
Mean (range)
62 (34–80)
NA
Mean (range)
44 (1.5–144)
NA
Shariat et al. [58]
2004
USA
630
1994–2002
Median (range)
60.9 (40–75)
Mean (range)
6.1 (0.1–99)
Median (range)
21.4 (1–101.3)
NA
p-PSA preoperative prostate-specific antigen, SD standard deviation, IQR interquartile range, NA data not applicable
Table 2
Tumour characteristics of the included studies
Author
Specimen
GS ≦ 7/˃ 7
Staging system
T stage
1–2/3–4
SM+/ SM−
No. of BCR (%)
Definition of BCR
Wettstein et al. [35]
292 /79
WHO/ISUP 2016
263/108
133/238
49 (13.2%)
Rising and verified PSA levels > 0.1 ng/ml
Xun et al. [6]
131/41
TNM 2002
NA
62/110
80 (46.5%)
The date of the first PSA elevated to 0.2 ng/ml
Meyer et al. [36]
879/24
TNM 2002
903/0
37/206
137(15.2%)
PSA level of ≧ 0.2 ng/ml and rising after RP
Gandaglia et al. [37]
55/39
TNM 2002
22/72
30/64
24 (25.5%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Shangguan et al. [33]
131/41
NA
NA
62/110
NA
Two consecutive increases in PSA ≧ 0.2 ng/ml
Zhang et al. [34]
136/32
TNM 2012
NA
30/138
NA
First PSA elevated to 0.2 ng/ml
Simon et al. [12]
368/43
NA
NA
353/58
70 (17%)
Single PSA concentration of > 0.2, two concentrations at 0.2 ng/ml
Sevcenco et al. [38]
6645/560
TNM 2009
NA
6137/1074
798 (11.1%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Pagano et al. [20]
90/90
TNM 2002
NA
74/106
120 (66.5%)
Two postoperative PSA values of ≧ 0.2 ng/ml
Moschini et al. [39]
647/364
NA
355/657
566/445
697 (69%)
PSA 0.4 ng/ml or greater
Mortezavi et al. [40]
86/14
NA
79/21
25/75
12 (12%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Mao et al. [41]
78/28
TNM 2002
63/43
20/86
31 (29.2%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Whalen et al. [29]
516/93
TNM 1997
435/174
483/126
73 (12%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Song et al. [42]
1722/415
NA
1899/248
2132/13,433
466 (21.8%)
Greater than 0.2 ng/ml
Reeves et al. [43]
1306/142
NA
1042/454
390/1089
238 (20.5%)
Greater than 0.2 ng/ml
Hashimoto et al. [5]
634/373
WHO 2004
677/160
243/594
102 (12.2%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Alvin et al. [44]
663/58
TNM 2010
497/228
311/414
104 (14%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Touijer et al. [13]
184/185
TNM 2010
46/323
138/231
201 (54%)
PSA ≧ 0.1 ng/ml with confirmatory rise
Ritch et al. [45]
783/196
TNM 2002
955/24
335/644
317 (32.4%)
Greater than 0.2 ng/ml
Kang et al. [21]
2575/459
TNM 2009
NA
974/2060
NA
A serum PSA value of 0.4 ng/ml or greater after RP
Fairey et al. [14]
133/96
TNM 2002
0/229
105/124
83 (36.2%)
Detectable PSA (ng/ml) followed by two consecutive confirmatory (1988–1994: PSA ≧ 0.3; 1995–2005: PSA ≧ 0.05; 2006–present: PSA ≧ 0.03)
Turker et al. [46]
167/164
TNM 1994
NA
80/251
70 (21%)
Higher than 0.2 ng/ml on 2 separate measurements 1 month apart
Sammon et al. [10]
760/34
AJCC 2002
592/202
162/632
107 (13.5%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Chen et al. [30]
109/43
NA
0/152
27/125
80 (52.6%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Sooriakumaran et al. [11]
900/44
NA
651/230
194/704
135 (15.2%)
Greater than 0.2 ng/ml
Lu et al. [31]
796/98
TNM 2010
703/191
250/644
277 (31%)
PSA ≧ 0.1 ng/ml with confirmatory rise
Iremashvili et al. [47]
1286/258
NA
NA
479/965
210 (15%)
Greater than 0.2 ng/ml
Connolly et al. [48]
95/65
NA
65/95
60/100
88 (55%)
Greater than 0.2 ng/ml
Busch et al. [49]
1538/307
NA
1802/9
537/1308
450 (24.4%)
PSA ≧ 0.1 ng/ml with confirmatory rise
Berge et al. [50]
553/24
TNM 2002
441/136
168/409
91 (16%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Lee et al. [51]
236/764
NA
NA
337/663
99 (9.9%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Alenda et al. [23]
1248/0
NA
NA
400/843
176 (16.9%)
PSA > 0.2 ng/mL
Fukuhara et al. [52]
332/32
TNM 2002
275/89
157/207
66 (18.1%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Cho et al. [53]
153/14
TNM 2002
126/45
58/109
15 (8.8%)
A serum PSA value of 0.4 ng/ml or greater after RP
Alkhateeb et al. [26]
1159/109
NA
853/415
264/1004
NA
A serum PSA value of 0.4 ng/ml or greater after RP
Jeon et al. [54]
190/45
TNM 2002
145/92
86/151
67 (28.3%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Schroeck et al. [55]
2855/359
NA
1991/1166
982/2212
706 (25.7%)
Greater than 0.2 ng/ml
Pavlovich et al. [56]
494/14
TNM 2002
416/92
69/439
102 (20%)
Two consecutive increases in PSA ≧ 0.2 ng/ml
Hong et al. [57]
361/11
TNM 2002
371/0
46/326
NA
First value greater than 0.2 ng/ml
Cheng et al. [8]
410/94
TNM 1997
348/156
174/330
157 (21.2%)
Two consecutive increases in PSA ≧ 0.1 ng/ml
Shariat et al. [58]
565/65
TNM 1997
NA
179/451
80 (12.7%)
First value greater than 0.2 ng/ml
GS Gleason score, SM+/SM surgical margin positive/surgical margin negative, BCR biochemical recurrence, NA data not applicable

Statistical analyses

All statistical analyses in this meta-analysis were performed by Stata 12.0 software (Stat Corp, College Station, TX, USA). The association between PSM and BCR outcome was presented as summary relative risk estimates (SRREs) and 95% CIs. Heterogeneity between studies was calculated by the chi-square-based Q test and I2. A value of p < 0.10 or I2 > 50% was considered as statistically significant heterogeneity. A random-effects model was used if heterogeneity was significant, and otherwise, a fixed-effects model was used. Sensitivity analysis was used to estimate the reliability of the pooled results via the sequential omission of each study. Subgroup analysis was performed to check whether the pooled HR was influenced by the region, publication year, mean age, sample size, mean preoperative PSA (p-PSA), median follow-up, and the cut-off value for BCR. To assess the stability of the combined HR, sensitivity analysis was performed by removing individual studies from the meta-analysis. Publication bias was assessed by funnel plots and was statistically determined by Egger’s linear regression. Statistical significance was defined as a two-tailed value of p < 0.05, except for the heterogeneity tests.

Results

Literature search and study characteristics

The full process of the systematic literature review is shown in Fig. 1. In accordance with the PRISMA search strategy, 1048 relevant studies were initially identified. After carefully reading each article, 780 studies were excluded for the following reasons: duplicates, letters, or reviews; or contained no evaluated margin status and focus on BCR. After the remaining studies (n = 268) were reviewed, additional studies were excluded because certain cohorts were studied more than once or relevant data were lacking. Forty-one high-quality retrospective studies comprising 37,928 patients (94–3294 per study) were ultimately included in the meta-analysis.
The primary characteristics of the included studies are summarised in Table 1. All studies were published between 2004 and 2017. Of these, 19 studies were conducted in an Asian country, and 12 were conducted in North America; the rest were conducted in Europe (7) or in multiple countries (3). The median follow-up period of the studies ranged from 14 to 174 months. All included studies were published in English, except for two that were in Chinese. Of all of the studies, 8 used laparoscopic RP, 7 used robot-assisted RP, and 3 used open RP. BCR was defined using different cut-off values (0.1 ng/ml, 0.2 ng/ml, 0.4 ng/ml) among the included studies, and the incidence of BCR after RP ranged from 8.8 to 66.5% according to the reported values (Table 2). NOS [17] was applied to assess the quality of the included studies, and the results showed that all of the studies were of high quality with an NOS score ≥ 7. (Additional file 1: Table S1).

Meta-analysis

The forest plots of the meta-analysis in our study demonstrated that PSM was associated with poorer BCR in RP patients by univariate analysis (random-effects model, pooled HR = 1.56; 95% CI 1.46, 1.66; p < 0.001; Fig. 2) and multivariate analysis (random-effects model, pooled HR = 1.35; 95% CI 1.27, 1.43; p < 0.001; Fig. 3). Given the large heterogeneity between the studies, subgroup analyses were performed by region, publication year, mean age, sample size, mean preoperative PSA (p-PSA), median follow-up, and the cut-off value for BCR. Although no significant modifiers accounting for the inter-study heterogeneity were detected, the results of subgroup analyses were consistent with the primary findings (Table 3).
Table 3
Overall analyses and subgroup analyses for the included studies
Analysis specification
No. of studies
Study heterogeneity
Effects model
Pooled HR (95% CI)
p value
I2 (%)
p heterogeneity
Univariate analysis (BCR)
 Overall
25
70.9
< 0.001
Random
1.56 (1.46,1.66)
< 0.001
 Geographical region
  Asia
12
72.1
< 0.001
Random
1.61 (1.43,182)
< 0.001
  Europe and North America
12
70.8
< 0.001
Random
1.50 (1.37,1.65)
< 0.001
 Date of publication
  ≥ 2014
13
81.8
< 0.001
Random
1.52 (1.36,1.70)
< 0.001
  < 2014
12
18.5
0.262
Fixed
1.61 (1.52,1.71)
< 0.001
 Mean age (years)
  ≥ 64
9
84
< 0.001
Random
1.62 (1.34,1.97)
< 0.001
  < 64
15
55.6
0.005
Random
1.54 (1.45,1.64)
< 0.001
 Sample size (cases)
  ≥ 500
10
40.1
0.09
Random
1.61 (1.52,1.70)
< 0.001
  < 500
15
76.9
< 0.001
Random
1.51 (1.33,1.71)
< 0.001
 Mean p-PSA (ng/ml)
  ≥ 10
7
81
< 0.001
Random
1.65 (1.38,1.97)
< 0.001
  < 10
14
58.5
0.003
Random
1.59 (1.48,1.71)
< 0.001
 Median follow-up
  ≥ 36 months
11
77.1
< 0.001
Random
1.49 (1.33,1.67)
< 0.001
  < 36 months
14
59.8
0.002
Random
1.61 (1.49,1.74)
< 0.001
 BCR (ng/ml)
  Cutoff value 0.1
4
0
0.775
Fixed
1.61 (1.49,1.72)
< 0.001
  Cutoff value 0.2
20
72
< 0.001
Random
1.58 (1.46,1.70)
< 0.001
  Cutoff value 0.4
1
Multivariate analysis (BCR)
 Overall
32
79.2
< 0.001
Random
1.35 (1.27,1.43)
< 0.001
 Geographical region
  Asia
14
67
< 0.001
Random
1.42 (1.29,1.55)
< 0.001
  Europe and North America
15
84.7
< 0.001
Random
1.31 (1.19,1.43)
< 0.001
  Multi-centred
3
71.9
0.029
Random
1.33 (1.00,1.78)
0.053
 Date of publication
  ≥ 2014
16
82.9
< 0.001
Random
1.27 (1.17,1.39)
< 0.001
  < 2014
16
67.2
< 0.001
Random
1.44 (1.32,1.56)
< 0.001
 Mean age (years)
  ≥ 64
8
62.5
0.009
Random
1.56 (1.32,1.85)
< 0.001
  < 64
22
81.5
< 0.001
Random
1.33 (1.24,1.43)
< 0.001
 Sample size (cases)
  ≥ 500
18
77.1
< 0.001
Random
1.40 (1.32,1.49)
< 0.001
  < 500
14
76.8
< 0.001
Random
1.28 (1.12,1.47)
< 0.001
 Mean p-PSA (ng/ml)
  ≥ 10
7
80.8
< 0.001
Random
1.36 (1.22,1.57)
< 0.001
  < 10
19
79
< 0.001
Random
1.35 (1.24,1.48)
< 0.001
 Median follow-up
  ≥ 36 months
16
79.6
< 0.001
Random
1.36 (1.24,1.46)
< 0.001
  < 36 months
15
79.8
< 0.001
Random
1.34 (1.21,1.47)
< 0.001
 BCR (ng/ml)
  Cutoff value 0.1
5
87.7
< 0.001
Random
1.22 (1.01,1.48)
0.044
  Cutoff value 0.2
23
71.3
< 0.001
Random
1.39 (1.30,1.48)
< 0.001
  Cutoff value 0.4
4
82.2
0.001
Random
1.34 (1.15,1.57)
< 0.001

The sensitivity analysis and publication bias

With a sensitivity analysis, the overall significance did not change when any single study was omitted. The summary relative risk estimate (SRRE) for BCR ranged from 1.52 (95% CI, 1.44–1.62) to 1.58 (95% CI, 148–1.68) (Fig. 4a) in univariate analysis and 1.34 (95% CI, 1.26–1.42) to 1.37 (95% CI, 1.29–1.45) (Fig. 4b) in multivariate analysis. These results indicated that the findings were reliable and robust. To test for publication bias, Egger’s linear regression was performed. No significant publication bias was detected between these studies regarding HR of BCR in univariate analysis (p-Begg = 0.971; Fig. 5a) and multivariate analysis (p-Begg = 0.401; Fig. 5b), respectively.

Discussion

With the increased public awareness and wide use of PSA-based screening, the number of patients diagnosed with PCa annually has been increasing [6]. Because RP provides superior cancer control and functional outcomes, this surgery has become a standard first-line treatment for eligible patients [18]. However, despite various advances in surgical technology, BCR has been reported in approximately 25–35% patients after RP and even more patients with intermediate–high risk [19]. Because BCR reportedly leads to distant metastasis and cancer death [20], it is necessary for men with BCR to undergo salvage radiation or hormonal therapy [11]. Therefore, identifying modifiable factors that affect the progression of BCR may help physicians in the selection of patients who are more likely to benefit from adjuvant multimodal therapy.
A number of nomograms have been developed to predict BCR after RP using either preoperative or postoperative variables [21]. Several clinical and pathologic factors have been included in these models, most of which cannot be altered by the treating physician (preoperative PSA [22], pathological T stage [5], pathological Gleason score [23]). The D’Amico risk stratification scheme [20] and Cancer of the Prostate Risk Assessment (CAPRA) score [24] have also been adopted in the urological community to predict the probability of BCR. Although these nomograms have been internationally validated, unfortunately, only a small number of them have predicted the probability of 5-year BCR with more than 70% accuracy [25]. Thus, efforts to improve existing outcome prediction tools for PCa are always encouraged.
PSM is a frequent situation encountered after radical prostatectomy (RP) for localised PCa with an occurrence ranging from 6 to 41% [9, 26, 27]. The incidence of PSM depends on various factors, including tumour biology, patient characteristics, pathological assessment method, and surgical technique [28]. We reported an overall PSM rate of 45.7% (17,339/37,928), which was slightly higher than other large series. Because the goal of surgical procedures is the complete removal of the tumour, the presence of PSM after RP is considered to be an adverse outcome associated with failure of the surgery to cure the PCa. However, the effects of PSM on clinical outcomes and the risk of BCR are still unclear. Several studies concluded that a PSM is an independent factor of BCR in patients with PCa after RP [11, 2931]. However, not all patients with PSM show recurrence according to other studies [27, 28, 32]. Moreover, several reports showed that the effect of PSMs on prognosis depends on certain clinical and pathological features of the disease [26].
To the best of our knowledge, this study is the most up-to-date and informative meta-analysis on the association between PSM and BCR risk. The results obtained in our meta-analysis are in line with the previous systematic review by Yossepowitch et al. In addition, our study presented a series of advancements in comparison with previous studies. First, we included more eligible studies with high quality. The search by Yossepowitch et al. included studies up to 2013. However, our search included 21 additional studies published from 2014 to 2017, thereby improving the evaluation on the effect and enabling more subgroup analyses. In addition, the studies retrieved for our analysis were not limited to English; two Chinese articles [33, 34] also met the criteria for inclusion. Similar to Yossepowitch et al., we identified a significant relationship between PSM and BCR in RP. However, we also found that the pooled result of PSM had a large heterogeneity in both univariate (I2 = 70.9%) and multivariate (I2 = 79.2%) analyses. Even though the cut-offs varied among the included studies (0.1 ng/ml, 0.2 ng/ml, 0.4 ng/ml), the subgroup analyses achieved results similar to both univariate and multivariate analyses (Table 3). Meanwhile, the sensitivity analysis of our study revealed that the omission of each study did not have a significant impact on the merged value of HR.
However, several limitations of this study should be considered. First and foremost, all included studies were retrospective; therefore, the data extracted from those studies may have led to potential inherent bias. Second, the criteria to determine the presence of PSM in the pathological specimen were inconsistent in the included studies, which may have potentially contributed to heterogeneity. Thus, rigorous morphological criteria should be established to standardise the diagnosis of PSM. Third, substantial heterogeneity was observed in the meta-analysis, and although we used the random-effects model according to heterogeneity, it still existed in our studies. Moreover, from the subgroup analyses, we believed that the heterogeneity was caused by differences in factors such as patient and tumour characteristics. Finally, studies with negative results tend to be unsubmitted or unpublished; grey literature was not included, meaning that language bias may have been present in this study.

Conclusions

In conclusion, this meta-analysis demonstrates that PSM has a detrimental effect on BCR risk in patients with PCa after RP and could therefore be considered to be an independent prognostic factor of BCR. Due to PSM’s excellent feasibility and low cost, this method should be more widely employed for BCR risk stratification and BCR prediction in patients with PCa. Given the inherent limitations of retrospective studies, further research is warranted, preferably with a longer follow-up period, to elucidate the potential role of PSM in influencing BCR risk.

Availability of data and materials

All data generated or analysed during this study are included in this published article (and its supplementary information files).
Not applicable.
I give my consent for information about my relative circle to be published in the World Journal of Surgical Oncology (WJSO-D-18-00097R1, Lijin Zhang). I understand that the information will be published without my relative’s (circle as appropriate) name attached, but that full anonymity cannot be guaranteed. I understand that the text and any pictures or videos published in the article will be freely available on the internet and may be seen by the general public. The pictures, videos, and text may also appear on other websites or in print, may be translated into other languages, or used for commercial purposes. I have been offered the opportunity to read the manuscript.

Competing interests

The authors declare that they have no competing interests.

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Metadaten
Titel
Positive surgical margin is associated with biochemical recurrence risk following radical prostatectomy: a meta-analysis from high-quality retrospective cohort studies
verfasst von
Lijin Zhang
Bin Wu
Zhenlei Zha
Hu Zhao
Yuefang Jiang
Jun Yuan
Publikationsdatum
01.12.2018
Verlag
BioMed Central
Erschienen in
World Journal of Surgical Oncology / Ausgabe 1/2018
Elektronische ISSN: 1477-7819
DOI
https://doi.org/10.1186/s12957-018-1433-3

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