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Preoperative Imaging Evaluation after Downstaging of Pancreatic Ductal Adenocarcinoma: A Multi-Center Study

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      Introduction: Evaluation of pancreatic ductal adenocarcinoma (PDAC) after chemoradiotherapy downstaging is challenging due to computed tomography (CT) overestimation of tumor extension and residual vascular involvement, limiting access to surgery to some patients with potentially resectable tumors. With this study, we wanted to assess which radiological findings are most reliable at pre-operative imaging in the evaluation of PDAC after chemoradiotherapy in order to achieve complete resection. Methods: We retrospectively enrolled 71 patients with locally advanced and borderline resectable PDAC who underwent neoadjuvant chemoradiotherapy. Pre-operative CT or magnetic resonance (MR) have been evaluated by three radiologists to assess major qualitative and quantitative parameters of lesions. Accuracy, sensitivity, and specificity compared to anatomopathological results were evaluated for each parameter. Cohen’s K-coefficient has been calculated to evaluate the inter-observer agreement (IOA). Both single and consensus lecture have been tested. Different dimensional cut-offs were tested to categorize tumors according to their major axis and to compare with anatomopathological diameter, tumor persistence, and margin infiltration. Results: A 25 mm cut-off was 67% sensitive, 90% specific, and 77% accurate in assessing real tumor dimension. 25 mm cut-off reported a 64% sensitivity, 78% specificity, and 69% accuracy in assessing R0 resection. Each 5 mm increment of major axis dimension there is an odds ratio (OR) 1.79 (95% CI 1.13–2.80, p = 0.012) for R+ resection. Imaging presence of the perivascular cuff is not associated with tumor persistence and resection margin infiltration ( p = 0.362). Lesion enhancement and pattern homogeneity were not accurate in determining tumor persistence. IOA was generally poor to fair, except for >25 mm cut-off classification where IOA was moderate. Diagnostic accuracy is superior in consensus lecture rather than single lecture. Conclusion: Imaging methods tend to underestimate PDAC resectability after neoadjuvant-CRT. IOA is poor to fair in evaluating most of the qualitative parameters of downstaged pancreatic adenocarcinoma. Surgery should be considered for downstaged borderline resectable PDACs, independently from perivascular cuff presence, especially for tumors smaller than 25 mm.

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      New response evaluation criteria in solid tumours: revised RECIST guideline (version 1.1).

      Assessment of the change in tumour burden is an important feature of the clinical evaluation of cancer therapeutics: both tumour shrinkage (objective response) and disease progression are useful endpoints in clinical trials. Since RECIST was published in 2000, many investigators, cooperative groups, industry and government authorities have adopted these criteria in the assessment of treatment outcomes. However, a number of questions and issues have arisen which have led to the development of a revised RECIST guideline (version 1.1). Evidence for changes, summarised in separate papers in this special issue, has come from assessment of a large data warehouse (>6500 patients), simulation studies and literature reviews. HIGHLIGHTS OF REVISED RECIST 1.1: Major changes include: Number of lesions to be assessed: based on evidence from numerous trial databases merged into a data warehouse for analysis purposes, the number of lesions required to assess tumour burden for response determination has been reduced from a maximum of 10 to a maximum of five total (and from five to two per organ, maximum). Assessment of pathological lymph nodes is now incorporated: nodes with a short axis of 15 mm are considered measurable and assessable as target lesions. The short axis measurement should be included in the sum of lesions in calculation of tumour response. Nodes that shrink to <10mm short axis are considered normal. Confirmation of response is required for trials with response primary endpoint but is no longer required in randomised studies since the control arm serves as appropriate means of interpretation of data. Disease progression is clarified in several aspects: in addition to the previous definition of progression in target disease of 20% increase in sum, a 5mm absolute increase is now required as well to guard against over calling PD when the total sum is very small. Furthermore, there is guidance offered on what constitutes 'unequivocal progression' of non-measurable/non-target disease, a source of confusion in the original RECIST guideline. Finally, a section on detection of new lesions, including the interpretation of FDG-PET scan assessment is included. Imaging guidance: the revised RECIST includes a new imaging appendix with updated recommendations on the optimal anatomical assessment of lesions. A key question considered by the RECIST Working Group in developing RECIST 1.1 was whether it was appropriate to move from anatomic unidimensional assessment of tumour burden to either volumetric anatomical assessment or to functional assessment with PET or MRI. It was concluded that, at present, there is not sufficient standardisation or evidence to abandon anatomical assessment of tumour burden. The only exception to this is in the use of FDG-PET imaging as an adjunct to determination of progression. As is detailed in the final paper in this special issue, the use of these promising newer approaches requires appropriate clinical validation studies.
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        Preoperative/Neoadjuvant Therapy in Pancreatic Cancer: A Systematic Review and Meta-analysis of Response and Resection Percentages

        Introduction Pancreatic ductal adenocarcinoma (PDAC) is the fourth leading cause of cancer-related mortality [1] and is associated with an extremely poor prognosis, reflected by a median survival of 5–8 mo and a 5-y survival probability of less than 5% when all stages are combined [1]–[3]. At present, the only chance for cure and prolonged survival is surgical resection with macroscopic tumor clearance. However, only approximately 10%–20% [1],[4] of patients are considered candidates for curative resection. The majority of patients (50%–60%) present with metastatic disease, and thus palliative chemotherapy remains the only option for almost all of these patients [5]. In a substantial number of patients (approximately 30%–40%) the disease is considered “locally advanced” at the time of diagnosis. This group of patients has been intensively discussed during the last years and neoadjuvant therapies have been proposed to achieve better local tumor control or tumor down-staging with a subsequent potentially resectable tumor [6]. Neoadjuvant therapy in this context is defined as any preoperative therapy aiming to convert unresectable to resectable tumors and/or to increase microscopic complete tumor resection rates. Unfortunately, however, no data regarding the role of neoadjuvant therapy for pancreatic cancer from randomized phase III trials are available. In addition, a thorough analysis of this group of patients has been hampered by the lack of an accepted and widely used definition of resectability and unresectability. For example, while current guidelines generally consider encasement/involvement of the superior mesenteric artery/celiac trunk as signs of unresectability [7],[8], portal vein/superior mesenteric vein involvement has been more critically discussed [9] and categories such as “borderline resectable” have been introduced [8]. Furthermore, all criteria depend heavily on the experience and technical expertise of the involved radiologists, gastroenterologists, and surgeons. Even following potential curative resection more than 80% of the patients ultimately die of the disease due to local recurrence and/or distant metastasis. The high rate of local recurrence [10] is predetermined by the microscopic frequently incomplete resections [11]–[13] as a result of the anatomical location of the tumor and the growth pattern of pancreatic cancer cells. Adjuvant therapy [14]–[16] has been established as the standard of care following resection for pancreatic adenocarcinoma. Here, solid data from randomized controlled trials [17]–[22] suggest that adjuvant chemotherapy (gemcitabine or 5-FU) is the standard treatment option. In contrast, there is still discussion regarding the role of adjuvant chemoradiation [20],[23] specifically in the subgroup of patients with positive resection margins [15]. The relatively high percentage of PDAC patients presenting with non-metastatic but “locally advanced” disease as well as the large number of microscopic incomplete resections [11],[13] should provide a strong rationale for a neoadjuvant approach. Although neoadjuvant therapy for pancreatic cancer has been proposed for more than two decades [24],[25], and although there is strong evidence of its benefit for other tumor entities, up to now there is no compelling evidence for a clinical benefit of neoadjuvant therapy in pancreatic cancer. Here, we systematically reviewed and performed a meta-analysis of the available data regarding neoadjuvant chemo- and/or radiotherapy with special emphasis on tumor response/progression rates, toxicities, and clinical benefit, i.e. resection probabilities and survival estimates. Methods Although no randomized phase III trials could be considered within this review, general recommendations from QUOROM [26] and the PRISMA revision [27] with regard to processing and reporting of results were taken into account (Text S1). Trial Criteria This systematic review and meta-analysis incorporated retrospective and prospective studies of patients with pancreatic and periampullary cancer with the following design: neoadjuvant radiochemotherapy, radiotherapy, or chemotherapy, followed by re-staging, and surgical exploration/resection in selected patients. Phase I–II clinical trials, cohort studies, and case series were included. Case reports were excluded as were reports of identical patient cohorts (if clearly identifiable). Search Strategy Trials were identified by searching MEDLINE, EMBASE, and the Cochrane Central Register of Controlled Trials from 1966 to December 2009 (Text S2). The search strategy included the following search keys: (“pancreas” or “pancreatic”) and (“cancer” or “carcinoma”) and (“neoadjuvant” or “preoperative”) and (“radiation” or “chemoradiation” or “chemotherapy”), without language restriction. The results were then hand-searched for eligible studies. Furthermore we searched the proceedings of the Gastrointestinal Cancers Symposium and ASCO Annual Meeting from 2004 to December 2009. In addition, reference lists of the selected trials were screened for any other relevant study. Prospective and ongoing trials were identified by searching the following prospective trials registers and databases (last search December 1, 2009): ISRCTN Register, Action Medical Research, Leukaemia Research Fund, Medical Research Council (UK), National Health Service Research and Development Health Technology Assessment Programme (HTA), National Institutes of Health (, The Wellcome Trust and the UK Clinical Trials Gateway, and The WHO International Clinical Trials Registry Platform ( including the Australian New Zealand Clinical Trials Registry (ANZCTR), Chinese Clinical Trial Register (ChiCTR), Clinical Trials Registry–India (CTRI), German Clinical Trials Register (DRKS), Iranian Registry of Clinical Trials (IRCT), Sri Lanka Clinical Trials Registry (SLCTR), and The Netherlands National Trial Register (NTR). The search strategy for these trials included the following search keys: ((“pancreas” or “pancreatic”) and (“cancer” or “carcinoma”) and (“neoadjuvant” or “preoperative”)) or ((“pancreas” or “pancreatic”) and (“cancer” or “carcinoma”) and (“non-metastatic” or “nonmetastatic”) and (“unresectable” or “non-resectable” or “locally advanced”)), without language restriction. Selection of Trials and Data Collection Two reviewers (SG, JK) independently assessed the eligibility of abstracts identified by the search. The full-text article of any trial that appeared to meet the inclusion criteria was retrieved for closer examination. Disagreements were resolved by consensus. The same reviewers extracted the data independently using standardized data collection forms. Data retrieved from the reports include publication details (year of publication, study center), methodological components, and trial characteristics, such as sample size, interventions (radiochemotherapy, radiotherapy, or chemotherapy), and outcome measures (Text S2). Included studies were subdivided into three groups: those studies analyzing patients with pancreatic and periampullary cancer who were judged resectable on preoperative staging (group 1), those studies analyzing patients whose tumors were judged borderline resectable or unresectable (subsequently termed non-resectable; group 2), and those studies that included all patients with localized non-metastatic disease (resectable and non-resectable). Studies were analyzed with respect to the utilized resectability criteria and grouped according to the current National Comprehensive Cancer Network (NCCN) criteria for resectability [28] if applicable. In cases where resectability criteria were not or not clearly stated, tumors were grouped according to the stated resectability category. Outcome Measures The primary outcome measures were proportions of tumor response categories (CR, PR, SD, PD) as well as percentages of exploration and resection. Secondary outcome measures included toxicity, morbidity, mortality, and survival. The authors aimed to unify definitions of tumor response across studies in accordance with the RECIST criteria [29]: Complete response: disappearance of all target lesions (radiographic) or no vital tumor cells (histopathological); partial response: 30% decrease of the target lesion (radiographic) or marked signs of tumor regression (histopathologic); progressive disease: 20% increase of the target lesion (radiographic), or distant metastases (radiographic or histopathologic); stable disease: no change or small changes that did not meet the above criteria. In case of discrepant radiological and histopathological response, the histopathological response was taken for calculation. Quality Assessment To assess the overall strength/quality of evidence for the various outcome parameters, a quality assessment was carried out in the style of the GRADEprofiler (GRADEpro. [Computer program]. Version 3.2 for Windows. Jan Brozek, Andrew Oxman, Holger Schünemann, 2008). Study design, study limitation, risk of bias, study inconsistency, indirectness, and imprecision were rated according to the GRADEprofiler. Study quality was classified as high, moderate, low, or very low. Outcome parameters were classified as critical, important but not critical, or of limited importance. Statistical Analysis The statistical software package R version 2.7.1 (R Foundation for Statistical Computing, Vienna, Austria) with function metaprop (R package: meta, Schwarzer 2008) was used for the statistical analyses. Pooled estimates of proportions with corresponding 95% confidence intervals were calculated on the base of the Freeman-Tukey double arcsine transformation [30],[31] within a random effect model framework. Heterogeneity of combined study results was assessed by inconsistency statistic (I2) and its connected chi-square test for heterogeneity, and I2 and the corresponding 95% confidence intervals were calculated. No formal test was conducted for purpose of subgroup comparisons and results were solely displayed in a comparative descriptive manner. References from literature [32] as well as especially conducted preliminary simulation studies suggest that unbiased pooled estimates of median survival times cannot be achieved by simple weighted averaging of medians. A more appropriate approach is achieved by averaging parameter estimates of a presumed density function of survival and recalculating the estimate of median from the pooled distribution parameter. A reasonable distribution of survival times which implies a time constant hazard rate corresponding to the sole distribution parameter λ is given by the exponential distribution. Following this assumption, a weighted estimate of population median (mp ) survival is derived by: where mi denotes the median survival within a study population i (with i from 1 to k) and wi refers a study specific weight function, and Σwi = 1. Since no sufficient information on patients at risk for median survival times was available from the considered studies, number of study participants (divided by the total number of evaluable patients) was used as weights. Confidence intervals for median estimates were not calculable and therefore the range of medians was provided instead of confidence limits. In order to analyze potential publication bias, funnel plots were created for the outcome parameters using a Web-based software tool (Eastern Region Public Health Observatory (erpho); Graphs were plotted using GraphPad Prism 5 for Windows (GraphPad, San Diego, CA). Analysis of Heterogeneity The general linear modeling framework to extract sources of variance (heterogeneity) from the study data was used. For this purpose, variables potentially explaining clinical incomparability and design incomparability, respectively, were considered in the meta-regression analysis following the terminology of Thompson [33]. These variables were resectability (yes, no, both, or not defined), resectability criteria (NCCN criteria [28], clearly defined criteria, not clearly defined, or no stated criteria), mean age of patients (5-y intervals), mean year of study interval (decades), chemotherapy (no, monotherapy, combination therapy), institution and study design (phase I, phase I/II, phase II, cohort study, case series, retrospective, prospective), and evaluation criteria (RECIST criteria [29], clearly defined criteria, not clearly defined, or no stated criteria). For purpose of a reliable statistical analysis, arcsine transformation was applied first to the main outcome parameters (proportions, e.g. fraction of resected and explored patients, respectively). The number of patients for each specific outcome parameter was considered as residual weight within the regression model and the fraction of explained variance was gathered for each model component. The main outcome parameters were (transformed) proportions; therefore percentages of explained variability have to be interpreted in a relative (comparative) manner rather than in an absolute one. Results From 515 initially retrieved studies, 111 studies published since 1980 were identified and included in this systematic review and meta-analysis (Figure S1, Table S1). Four studies overlapped with four of the 111 studies, and were therefore excluded. In the same time period, 85 reviews regarding neoadjuvant therapy in pancreatic cancer were published. The number of published original and review articles increased steadily within the last 15 years (Figure 1). 10.1371/journal.pmed.1000267.g001 Figure 1 Number of identified original studies (n = 111) and reviews (n = 85) per year (1980–2009). The 111 reviewed trials included 4,394 patients. Seventeen centers published more than 1 study, altogether accounting for 73 of the 111 studies (Table S1). Eight of the 17 centers published 2 studies. The University of Texas M.D. Anderson Cancer Center (Houston, TX) and the Fox Chase Cancer Center (Philadelphia, PA) published 12 and 11 studies, respectively (Table S1). Other centers such as University of Osaka (Japan), the University of Marseille (France), and the Duke University (Durham, NC) published 8, 6, and 5 studies, respectively. The potentially overlapping patient populations were difficult to calculate since the information of which patients were included in which analysis could not always be retrieved. Using the study periods, study protocols, and a conservative estimate, there was a maximum of 17% overlapping patient populations. Of the 111 included studies, 78 studies were prospective and 33 retrospective. There were 15 phase I, 13 phase I/II, and 28 phase II studies, as well as 14 cohort studies and 41 case series. No phase III trials have been published so far. A systematic search of clinical trial databases for pancreatic cancer trials identified 17 neoadjuvant trials (all phase I–II trials) and 23 trials for non-resectable but non-metastatic pancreatic cancer, i.e. potentially neoadjuvant trials (Table S2). The 111 analyzed studies reported on PDAC that generally included pancreatic head, corpus, and tail tumors without separate analysis regarding tumor localization. The studies included a median (IQR) of 31 (19–46) patients (Table 1). Ten of the 111 studies included in addition to pancreatic cancer a few patients with other periampullary tumors (i.e. ampullary, distal bile duct, and duodenal cancer), without separate analysis of the different entities. In 84 studies (76%), it was explicitly stated that histological or cytological tumor diagnosis was obtained before therapy. The age of the included patients varied, as did its reporting. The median of reported age of the patients in the 94 assessable studies was 62.5 y and was similar in the analyzed groups (group 1: 62 y, group 2: 62 y). 10.1371/journal.pmed.1000267.t001 Table 1 Summary of included studies in the different defined groups. Group Total Number of Studies (%) Patients per Study Median (IQR) All patients 111 31 (19–46) Group 1 (tumor resectable before treatment) 35 (31.5%) 32 (20–50) Group 2 (tumor non-resectable before treatment) 57 (51.4%) 27 (18–38) Group 3 (both or not defined) 19 (17.1%) 38 (24–82) Chemotherapy Chemotherapy was applied as neoadjuvant treatment in 107 of the 111 studies (96.4%). Different combinations of chemotherapies/agents and dosages were tested, as 56 of the studies were phase I–II trials. The main agents were gemcitabine, 5-FU (and oral analogues), mitomycin C, and platinum compounds (Figure 2A). In the trials that used only one regimen (n = 79), 43 (54.4%) were performed using 5-FU or its oral analogues. 5-FU monotherapy was given in 14 (17.7%) of the studies. Thirty-six (45.6%) of the studies used a gemcitabine-based regimen, and of those, 18 (22.8%) studies applied gemcitabine monotherapy. 5-FU and gemcitabine combinations were used in 3 studies. Several studies compared different schemes or agents. Five studies were performed comparing gemcitabine with 5-FU or capecitabine, two studies comparing gemcitabine with cisplatin, two gemcitabine with 5-FU/cisplatin, and another three gemcitabine with 5-FU/mitomycin C. A further 16 studies included different agents and combinations (some for only few patients) (Table S1). Twelve trials included taxanes (docetaxel/paclitaxel) in different combinations or as monotherapy (n = 3). Five of the 107 studies included antibodies or tyrosine kinase inhibitors (bevacizumab, cetuximab, erlotinib) in the chemotherapeutic regimen. There were 44 studies using single agents (alone or in comparison) and 48 studies using combination therapies. In 15 studies both single agents and combination therapies were utilized. 10.1371/journal.pmed.1000267.g002 Figure 2 Depiction of utilized chemotherapy and radiotherapy. (A) Schematic overview of the used chemotherapeutic agents. diff. regimen, studies comparing/using different drug regimen (n = 28); no CTx, no chemotherapy applied (only radiotherapy). (B) Schematic overview of the applied radiation doses. Studies are summarized within a range of applied doses. Data included are per protocol, not all patients received the stated dose. diff. regimen, different radiation doses applied; not specified, radiation applied, dose not specified; no RTx, no radiotherapy applied (only chemotherapy). Radiotherapy In 104 of the 111 studies (93.7%) patients received neoadjuvant radiotherapy. In three studies the exact radiation dose was not given. Doses applied ranged from 24 Gy to 63 Gy (Figure 2B). In 52 of the 104 studies that included radiotherapy the patients received doses between 45 and 50.4 Gy. In 14 studies different doses and radiation schedules were compared. Most patients received 1.8 Gy/fraction (50/104 studies), 2 Gy/fraction (15/104), or 3 Gy/fraction (10/104). In 13 studies intraoperative radiation (IORT) was applied with doses between 10 and 30 Gy. Since in most of those studies only few patients received IORT, this aspect was not further analyzed. Toxicity Data regarding treatment-related toxicity were available for 63 of 111 studies. For subsequent analysis, only severe (grade 3/4) toxicity (National Cancer Institute Common Toxicity Criteria; was taken into account. Grade 3/4 toxicity for neoadjuvant therapy was estimated at 29.4% (CI 23.1%–36.1%) for all patients and was comparable for initially resectable (26.3%, CI 15.8%–38.3%) and patients with non- resectable tumors (“non-resectable tumor patients”) (31.1%, CI 22%–40.9%) (Table 2). Recent randomized controlled trials for adjuvant therapy report grade 3/4 toxicity rates for chemotherapy of 8.4%–22% (only neutropenia [21]) and 14.7% (all toxicity [20]). The reported grade 3/4 toxicity rates for radiochemotherapy were 9%–58% (only hematological toxicity [34]) and 22.2%–79% (all toxicity [20]). 10.1371/journal.pmed.1000267.t002 Table 2 Estimates of grade 3/4 toxicity of neoadjuvant treatment including the 95% confidence interval from the random effect model and number of assessable studies for each group (n). Group Grade 3/4 Toxicity All patients 29.4% [23.1%–36.1%]I2 = 91.3% [89.6%–92.7%](n = 63) Tumor resectable before treatment (group 1) 26.3% [15.8%–38.3%]I2 = 92.8% [90.3%–94.6%](n = 22) Tumor non-resectable before treatment (group 2) 31.1% [22.0%–40.9%]I2 = 91.6% [89.3%–93.5%](n = 33) Tumor Response Tumor response frequency for neoadjuvant chemo- and/or radiation therapy was evaluated in the different studies according to either radiographic or clinical response evaluation before exploration or histopathological response after resection. Six studies (5.4%) explicitly stated that the RECIST criteria [29] were utilized. In 44 studies (39.6%) the criteria to assess tumor response were clearly stated, whereas in 61 studies (55%) criteria were either not clearly defined or not stated. For the whole study population the estimated fraction of patients with complete response was 3.9% (CI 3%–4.9%) (Figure 3) and with partial response 29.1% (CI 24.5%–34%) (Figure 4). Stable disease was averaged to 43.9% (CI 37.9%–50%) in all patients and tumor progression under therapy occurred by estimation in 20.8% (CI 17.3%–24.6%) of the patients. Interestingly the pooled percentages did not vary much in the two groups of initially deemed resectable and non-resectable tumor patients (Table 3). Thus, complete/partial responses were 3.6%/30.6% and 4.8%/30.2% for groups 1 and 2, respectively; whereas progressive disease was estimated to 20.9% (CI 16.9%–25.3%) and 20.8% (CI 14.5%–27.8%) of primarily staged resectable and non-resectable tumor patients. Comparing tumor response frequencies for patients treated with mono chemotherapy (n = 44) versus combination chemotherapy (n = 48) revealed complete and partial responses of 2.2% (CI 1.3%–3.3%) and 25.8% (CI 20.2%–31.8%) versus 5.3% (CI 3.8%–7%) and 34.7% (CI 28.9%–40.9%) (Table 4). 10.1371/journal.pmed.1000267.g003 Figure 3 Estimates of complete response percentages in patients following neoadjuvant therapy and re-staging including the 95% confidence interval from the random effect model and number of patients for each study (n). 10.1371/journal.pmed.1000267.g004 Figure 4 Estimates of partial response percentages in patients following neoadjuvant therapy and re-staging including the 95% confidence interval from the random effect model and number of patients for each study (n). 10.1371/journal.pmed.1000267.t003 Table 3 Estimates of exploration and resection percentages after neoadjuvant treatment and restaging, and estimates of patients with complete response/partial response, stable disease, and progressive disease including the 95% confidence interval from the random effect model and number of assessable studies for each group (n). Group Complete Response Partial Response Stable Disease Progressive Disease Explored/All Resected/All R0/Resected Resected/Explored All patients 3.9%[3.0%–4.9%]I2 = 44.7%[28.1%–57.5%](n = 82) 29.1%[24.5%–34.0%]I2 = 86.9%[84.2%–89.1%](n = 75) 43.9%[37.9%–50.0%]I2 = 87.7%[85%–89.9%](n = 63) 20.8%[17.3%–24.6%]I2 = 81.4%[77.3%–84.8%](n = 78) 69.5%[62.1%–76.4%]I2 = 95.5%[94.9%–96%](n = 88) 50.7%[44.0%–57.4%]I2 = 95.2%[94.6%–95.7%](n = 111) 79.6%[74.8%–83.9%]I2 = 81.3%[77.4%–84.6%](n = 86) 77.9%[72.4%–82.9%]I2 = 89%[87%–90.6%](n = 88) Tumor resectable before treatment (group 1) 3.6%[2.0%–5.5%]I2 = 53.9%[29.3%–70%](n = 28) 30.6%[20.7%–41.4%]I2 = 90.3%[86.7%–92.9%](n = 23) 42.1%[30.5%–54.1%]I2 = 91.4%[88.4%–93.6%](n = 23) 20.9%[16.9%–25.3%]I2 = 66.9%[51.2%–77.5%](n = 29) 88.1%[82.9%–92.4%]I2 = 86.2%[81.5%–89.7%](n = 32) 73.6%[65.9%–80.6%]I2 = 90.1%[87.3%–92.3%](n = 35) 82.1%[73.1%–89.6%]I2 = 89.3%[85.5%–92%](n = 26) 85.7%[78.9%–91.2%]I2 = 88.6%[85%–91.4%](n = 32) Tumor non-resectable before treatment (group 2) 4.8%[3.5%–6.4%]I2 = 33.9%[3.4%–54.8%](n = 42) 30.2%[24.5%–36.3%]I2 = 81.8%[75.9%–86.2%](n = 40) 41.6%[34.6%–48.7%]I2 = 75%[64.2%–82.6%](n = 29) 20.8%[14.5%–27.8%]I2 = 85.4%[80.7%–88.9%](n = 36) 46.9%[36.9%–57.1%]I2 = 93.7%[92.2%–94.8%](n = 41) 33.2%[25.8%–41.1%]I2 = 92.5%[91%–93.7%](n = 57) 79.2%[72.4%–85.2%]I2 = 70.2%[59.7%–78%](n = 45) 69.9%[61.2%–77.9%]I2 = 79.9%[73.3%–84.9%](n = 41) 10.1371/journal.pmed.1000267.t004 Table 4 Estimates of percentage of responses and resections in patients receiving mono chemotherapy versus combination chemotherapy groups including the 95% confidence interval from the random effect model and number of assessable studies for each group (n). Group Mono Chemotherapy Combination Chemotherapy Complete response[95% CI](number of studies assessable) 2.2% [1.3%–3.3%]I2 = 20.8% [0%–49.7%](n = 30) 5.3% [3.8%–7.0%]I2 = 48.3% [25.5%–64.1%](n = 41) Partial response[95% CI](number of studies assessable) 25.8% [20.2%–31.8%]I2 = 78.8% [70.3%–84.9%](n = 30) 34.7% [28.9%–40.9%]I2 = 79.5% [72.1%–85%](n = 35) Resection rate (group 1)[95% CI](number of studies assessable) 80.8% [66.1%–92.1%]I2 = 93.9% [91.2%–95.7%](n = 13) 66.2% [57.9%–74.0%]I2 = 77.1% [62.6%–86%](n = 19) Resection rate (group 2)[95% CI](number of studies assessable) 27.3% [18.1%–37.5%]I2 = 87.7% [82.7%–91.3%](n = 22) 33.0% [25.2%–41.3%]I2 = 87.3% [82.9%–90.6%](n = 29) Exploration and Resection Operations performed included explorative laparotomies, palliative bypass procedures, and curative resections, e.g. partial pancreatico-duodenectomies, distal pancreatectomies, and total pancreatectomies. Studies were analyzed for patients explored and resected after restaging. All 111 studies included data for resection. Seven studies (6.3%) explicitly used the NCCN guidelines of resectability for non-metastatic pancreatic cancer [28]. Forty-five studies (40.5%) clearly defined the resectability criteria assessing most often the vascular involvement or classified the resectability according to the maximal tumor dimension. In 59 studies (53.2%), resectability criteria were not clearly stated (e.g. judged by single surgeons or an interdisciplinary team) or not stated at all. In group 1 including the patients who were staged to be resectable before neoadjuvant treatment resectability estimated to 73.6% (CI 65.9%–80.6%) (Figure 5, Table 3), whereas in group 2 including the patients who were staged non-resectable before treatment the averaged probability for resectability was 33.2% (CI 25.8%–41.1%) (Figure 5, Table 3). As shown in Table 3, in the assessable studies the percentage of exploration for the entire group was 69.5% (CI 62.1%–76.4%) and 77.9% (CI 72.4%–82.9%) of these patients were resected. Of the patients deemed resectable before treatment, 88.1% (CI 82.9%–92.4%) were explored after restaging, and of those 85.7% (CI 78.9%–91.2%) could be resected. In group 2, 46.9% (CI 36.9%–57.1%) of the patients were explored. Of them, 69.9% (CI 61.2%–77.9%) could be resected successfully (Table 3). Interestingly the estimated fraction of R0 resections were comparable between patients in group 1 (82.1%; CI 73.1%–89.6%) and patients in group 2 (79.2%; 72.4%–85.2%) (Table 3). To analyze potential publication bias, funnel plots were created (Figure 6) that demonstrated heterogeneity (see below) but no considerable imbalance (no reasonable evidence for publication bias) neither for the group of patients with initially resectable tumors (“resectable tumor patients”) nor for the non-resectable tumor patients. There were three considerable outliers in the non-resectable group (Figure 6B). Omission of these trials in another supportive meta-analysis regarding resection rates demonstrated an estimated resection probability of 30% (CI 24%–36%), which was similar to the estimated proportion of 33% (CI 26%–41%) for the entire group of non-resectable tumor patients. 10.1371/journal.pmed.1000267.g005 Figure 5 Estimates of resection percentages in patients following neoadjuvant therapy and re-staging including the 95% confidence interval from the random effect model and number of patients for each study (n). Studies analyzing initially resectable tumor patients are depicted in blue, initially non-resectable tumor patients in green, and those including both (or not defined) in black. 10.1371/journal.pmed.1000267.g006 Figure 6 Funnel plots for the resection rate for studies analyzing initially resectable (A) and non-resectable (B) tumor patients. Green line, average proportion; dashed blue line, upper and lower 3 SD limits; solid blue line, upper and lower 2 SD limits. Analyzing resection frequencies for patients treated with mono chemotherapy versus combination chemotherapy revealed that in the group of initially resectable tumor patients, the averaged fraction of resections for patients receiving monotherapy was 80.8% (CI 66.1%–92.1%) and for combination chemotherapy 66.2% (CI 57.9%–74%). In contrast, in patients with locally advanced/unresectable tumors, resections were more frequent in the group of patients who received combination chemotherapy with 33% (CI 25.2%–41.3%) in comparison to monotherapy with 27.3% (CI 18.1%–37.5%) (Table 4). Morbidity and Mortality Data regarding morbidity and mortality following neoadjuvant treatment and pancreatic resection were presented in 50 and 85 of 111 studies, respectively. Perioperative morbidity was estimated at 34.2% (CI 28.3%–40.4%) for all patients (Table 5), which is within the range of reported morbidity data of 30%–55% for major pancreatic (head) resections [35]. In-hospital mortality after neoadjuvant treatment and tumor resection was estimated at 5.3% (CI 4.1%–6.8%) for all patients (Table 5), which is at the upper limit of the 2%–5% mortality rates that have been reported in large series and surveys for major pancreatic resections at high volume centers [35]–[37]. Interestingly, morbidity and mortality rates were estimated higher in the group of initially non-resectable versus resectable tumor patients (morbidity: 39.1% versus 26.7%, mortality: 7.1% versus 3.9%) (Table 5). 10.1371/journal.pmed.1000267.t005 Table 5 Estimates of morbidity and mortality in patients undergoing pancreatic resection following neoadjuvant therapy including the 95% confidence interval from the random effect model and number of assessable studies for each group (n). Group Morbidity Mortality All patients 34.2%[28.3%–40.4%]I2 = 75.8%[68.2%–81.5%](n = 50) 5.3%[4.1%–6.8%]I2 = 29.2%[7%–46.1%](n = 85) Tumor resectable before treatment (group 1) 26.7%[20.7%–33.3%]I2 = 67.2%[48.8%–79%](n = 22) 3.9%[2.2%–6.0%]I2 = 51.9%[26.9%–68.3%](n = 30) Tumor non-resectable before treatment (group 2) 39.1%[29.5%–49.1%]I2 = 67.5%[49.8%–78.9%](n = 23) 7.1%[5.1%–9.5%]I2 = 0%[0%–23.4%](n = 43) Survival Analysis Estimates of population median survival times were calculated as described and are provided with ranges from evaluable studies. Survival times for the individual studies were calculated from the time of diagnosis/start of neoadjuvant therapy in 47 trials and from surgery/resection in 4 trials. In 60 studies no detailed information regarding survival or survival calculations were provided. The longest median survival (23.3 mo, range 12–54 months) was estimated for the group of initially staged resectable tumor patients who were resected after neoadjuvant treatment (Table 6, Figure 7). The initially non-resectable staged patients reached an estimated median survival of 20.5 (range 9–62) mo following resection. The estimated median survival for the entire group of resected patients was 22.4 (range 9–62) mo. As expected, the median survival of the entire group of patients who did not undergo resection was shorter with 9.5 (range 6–21) mo. The patients who were initially classified as resectable and did not undergo resection after pretreatment survived an estimated median of 8.4 (range 6–14) mo, compared to 10.2 (range 6–21) mo of patients initially diagnosed as unresectable who did not undergo resection. Estimated 1- and 2-y survival probabilities for resected patients in group 1 were 77.9% and 47.4% and for group 2 79.8% and 50.1% (Table 6). 10.1371/journal.pmed.1000267.g007 Figure 7 Summary overview of survival and resection percentages of different groups of patients with pancreatic cancer. Note that survival estimates derive from this systematic review and referenced studies. 10.1371/journal.pmed.1000267.t006 Table 6 Estimates of median survival times (mp ) in months and survival probabilities. Group Estimated Median Survival (mp ) Estimated Survival Probability (Resected) Resected (Range) Not Resected (Range) 1 Year (Range) 2 Year (Range) All patients 22.4(9–62)(n = 70) 9.5(6–21)(n = 51) 78.9% (0%–100%)I2 = 48.1% [28.7%–62.3%](n = 54) 49.2% (0%–82%)I2 = 85.2% [80.5%–88.7%](n = 37) Tumor resectable before treatment (group 1) 23.3(12–54)(n = 27) 8.4(6–14)(n = 19) 77.9% (48%–100%)I2 = 70.7% [52.6%–81.8%](n = 18) 47.4% (25%–70%)I2 = 69.1% [42.2%–83.4%](n = 11) Tumor non-resectable before treatment (group 2) 20.5(9–62)(n = 29) 10.2(6–21)(n = 25) 79.8% (0%–100%)I2 = 92.1% [89.8%–93.9%](n = 29) 50.1% (0%–82%)I2 = 88.6% [84%–91.9%](n = 21) n, number of assessable studies for each group. Analysis of Heterogeneity and Quality Assessment The results of meta-regression, particularly the amount of explained heterogeneity (variance components), are summarized in Table 7. For the purpose of sensitivity analysis, particularly to investigate sensibility of results with regard to model considerations (prospective under- and/or over-fitting), both univariable and multivariable models (simultaneously including all potential explanatory factors) were employed. In total, 17 institutions could be identified which contributed more than one study to the total number of trials. There were two institutions with more than 10 trials considered in our systematic review and meta-analysis. The results of the multivariable meta-regression analysis revealed that the amount of heterogeneity could be explained from about 13% to 35% by differences between institutions (considered as random effect variable). The highest impact of centers was observed regarding toxicity (34.8%) despite simultaneous consideration of chemotherapy, which corresponds to the next highest component of total variability at least in the multivariable analysis. Study design showed some impact on response evaluation (explained variability: up to 11%) and morbidity (up to 9%). Mean age of patients and study period are considerable explanatory variables for heterogeneity in morbidity and in-hospital mortality with an estimated amount of explained heterogeneity of about 10%. Heterogeneity of resection and exploration rates could mainly be deduced to resectability as well to differences between institutions and there was no sufficient explanation supported by the other potentially influencing variables. In general, the results of univariable and multivariable heterogeneity analysis were quite comparable. However, some range in attributable source of outcome variability was apparent for resectability (concerning resection and exploration rates), institution (concerning response rates), and chemotherapy (concerning complete response rates and toxicity) (Table 7). Quality assessment according to the GRADEprofiler regarding toxicity analysis, response evaluation, resection and exploration rates, morbidity, mortality, and survival analysis is presented in Table 8. 10.1371/journal.pmed.1000267.t007 Table 7 Multivariable meta-regression analysis for different variables as indicated and described in the Methods section. Potential Explanation Factor Variable Resection Rate Exploration Rate CR PR SD PD Toxicity Morbidity Mortality Institution 16.7% (17.4%) 13.3% (15.0%) 30.2% (31.9%) 20.9% (16.7%) 27.2% (10.7%) 12.8% (24.9%) 34.8% (35.2%) 20.8% (14.3%) 22.5% (19.6%) Study design 1.2% (2.9%) 0.6% (1.6%) 3.1% (1.0%) 10.7% (4.0%) 4.1% (1.8%) 3.6% (6.9%) 3.8% (4.6%) 8.7% (2.0%) 2.3% (1.6%) Chemotherapy 2.1% (3.1%) 0.8% (1.6%) 0.6% (8.1%) 6.0% (7.2%) 1.6% (0.8%) 0.2% (0.4%) 10.4% (2.4%) 0.1% (0.5%) 3.1% (6.8%) Mean year of study interval (decades) 2.0% (1.9%) 1.1% (0.2%) 0.2% (2.0%) 0.6% (6.7%) 2.3% (1.0%) 0.9% (7.0%) 2.2% (1.5%) 3.2% (2.0%) 10.4% (10.6%) Mean patient age (5-y intervals) 1.1% (1.1%) 1.2% (0.6%) 2.7% (1.1%) 3.4% (3.4%) 1.5% (1.8%) 1.4% (1.7%) 3.5% (2.6%) 9.9% (4.1%) 9.9% (4.6%) Response evaluation criteria 1.5% (3.4%) 2.7% (3.6%) 2.4% (0.1%) 2.6% (0.3%) Resectability 14.0% (9.0%) 25.5% (10.5%) 1.0% (0.9%) 0.0% (2.6%) 4.1% (0.9%) 1.1% (8.1%) 0.3% (0.2%) 2.2% (4.9%) 0.6% (0.2%) Resectability evaluation criteria 0.1% (0.7%) 1.4% (0.7%) The fraction of explained variance is given in %. Values in parentheses represent the fraction of explained variance in % from univariable analysis. CR, complete response; PD, progressive disease; PR, partial response; SD, stable disease. 10.1371/journal.pmed.1000267.t008 Table 8 Quality assessment. Category Outcome Resection Rate Exploration Rate Response Evaluation Toxicity Morbidity Mortality Median Survival 1 y/2 y Survival Number of studies (range) 35–111 32–88 2–82 22–63 22–50 30–85 19–70 11–54 Study design Phase I–II trials Phase I–II trials Phase I–II trials Phase I–II trials Phase I–II trials Phase I–II trials Phase I–II trials Phase I–II trials Cohort studies Cohort studies Cohort studies Cohort studies Cohort studies Cohort studies Cohort studies Cohort studies Case series Case series Case series Case series Case series Case series Case series Case series Limitations No serious limitation No serious limitation No serious limitationa No serious limitation No serious limitationb No serious limitationb No serious limitationc No serious limitationd Inconsistency Serious inconsistencye Serious inconsistencye Serious inconsistencye No serious inconsistencyf No serious inconsistencyg No serious inconsistencyh Serious inconsistencye Serious inconsistencye Indirectness i Imprecisionj No serious imprecisionk No serious imprecisionk No serious imprecisionk No serious imprecisionl Serious imprecisionm Serious imprecisionn Serious imprecisiono Serious imprecisiono Other considerations Studies weighted by number of initial patients Studies weighted by number of initial patients Quality ++ ++ ++ +++ ++ ++ + + Importance Critically important Important Important Important Important Critically important Critically important Critically important The quality assessment for the indicated outcome parameters was carried out according to the grade profiler as described in the Methods section. +, very low; ++, low; +++, moderate. a Separated evaluation of response categories, several evaluation criteria, proportions experiencing each type of response are not independent. b Based only on resected patients. c Assumption of uniform (exponential) distributed survival times. d Different trials for estimating 1 y/2 y survival. e High heterogeneity which could not be sufficiently explained by potential sources of variation within the meta-regression analysis. f Obvious heterogeneity partly explained by different chemotherapy treatment regimes within the trials. g Obvious heterogeneity partly explained by differences in mean patient age and study design between the trials. h No considerable heterogeneity obvious from the data. i Since no direct comparison was feasible for any considered outcome measurement, indirectness has to be fixed as “very serious” for the entire topic of the investigation. j For the same reason no particular measure of precision (e.g. confidence intervals) was available for any single trial considered; therefore, imprecision is rather crude assessed in reference to the number of study participants within any meta-analysis. k Substantial sample sizes per study: median (IQR): 30 (18 to 47). l Substantial sample sizes per study: median (IQR): 29 (19 to 39). m Insufficient sample sizes per study: median (IQR): 16 (7 to 25). n Insufficient sample sizes per study: median (IQR): 13 (6 to 25). o No sufficient information about patients at risk. Discussion This comprehensive review of neoadjuvant therapy in pancreatic cancer aimed to evaluate the key issues, including aspects of response and survival, and to highlight current problems and drawbacks. Neoadjuvant protocols have been analyzed with increasing frequency (Figure 1), as they offer a number of hypothetical advantages over adjuvant (postoperative) therapy, such as shorter therapy and higher therapy completion rates, tumor down-staging with higher (R0) resection rates, and importantly better patient selection. Thus, neoadjuvant treatment and reassessment may identify those patients (both initially resectable and non-resectable) presenting with rapid progressive or disseminated disease at restaging who therefore have a very poor prognosis and for whom surgery is unlikely to provide any benefit. On the other hand, there is the potential risk for tumor progression during neoadjuvant therapy, i.e. patients with initially resectable tumors might present with local or distant tumor progression at restaging, which might not have occurred in the setting of an initial tumor resection. In addition, neoadjuvant treatment protocols usually require histological confirmation before initiation of therapy, resulting in additional invasive diagnostic measures. Clearly, only randomized controlled trials can clarify which of the hypothetical advantages/disadvantages are real and which ones are not. There is only one phase III randomized controlled trial being carried out comparing neoadjuvant therapy and surgery with surgery alone (NCT00335543) [38]. This multicenter trial has been recruiting patients since June 2003 and has currently enrolled less than a third of the originally planned 254 patients. Due to the exceedingly slow recruitment, the study will be terminated before reaching the target population. In the future, phase III trials have to be carried out using already established protocols comparing neoadjuvant therapy followed by exploration and possibly resection, with immediate exploration and resection if possible (and additional standard palliative or adjuvant therapies in both arms). As our data point out, this would be especially relevant in the group of borderline resectable/unresectable tumors. As a prerequisite for such trials, standard definitions of resectability and objective computed tomography criteria should be applied. The reasons why no other phase III randomized trials for neoadjuvant therapy in pancreatic cancer have been carried out or are currently recruiting patients is not known. It might be speculated that patient recruitment is a problem. However, given the high rate of “neoadjuvant” treated patients with locally advanced/unresectable tumors [6], this argument does not seem to be valid, at least not in this group of patients. Another important problem might be the difficulty to achieve a histological/cytological proof of the tumor; however, this would also apply to palliative therapy in most cases. Obviously, there is a plethora of different chemotherapeutic/radiotherapeutic regimens being used in the neoadjuvant setting (Figure 2, Table S1), and it might be difficult to agree on a specific protocol for a large multi-institutional study. In addition, standardized and widely accepted definitions of resectability criteria are lacking. And finally, it might also be more tempting in terms of funding and publications to perform small phase I–II trials with newer chemotherapeutic agents and radiation protocols, instead of phase III trials with already established protocols. In contrast to the lack of phase III randomized controlled trials, we have identified 111 relevant studies, including 56 phase I–II trials of neoadjuvant therapy in pancreatic cancer. Neoadjuvant Therapy for Resectable Pancreatic Cancer In the group of patients deemed resectable before neoadjuvant treatment, 88.1% of the patients were explored after restaging and of those 85.7% were resected. In all, 73.6% of the patients who were judged resectable were resected after neoadjuvant treatment. This rate is similar to published resection rates of 78%–96% in patients with resectable tumors that are explored without neoadjuvant treatment [4],[39]. Grade 3/4 toxicities observed for neoadjuvant therapy (i.e. radiochemotherapy in 96.4%) were higher than the reported rates for adjuvant chemotherapy but within the range of adjuvant radiochemotherapy. An estimated median survival of 23.3 mo was observed for the group of resectable tumor patients who were resected after treatment. This is within the range of the median survival of 20.1–23.6 mo observed in patients who are resected followed by adjuvant chemotherapy [20],[21],[40], and longer than the median survival of 16.9–20.2 mo for patients who do not receive adjuvant therapy (Figure 7) [20],[21]. In conclusion, the available evidence for resectable pancreatic cancer points to similar resection rates with or without neoadjuvant therapy and similar survival rates comparing neoadjuvant therapy followed by resection versus resection followed by adjuvant therapy (Figure 7). Neoadjuvant Therapy for Non-resectable Pancreatic Cancer In our analysis 46.9% of the patients initially staged unresectable underwent surgical exploration. Of them, 69.9% could be resected successfully, leading to a resectability rate after neoadjuvant treatment in this group of patients of a relevant 33.2% (with comparable R0 resection rates as in the group of initially resectable tumor patients). Morbidity and mortality rates following resection were estimated higher in this group of patients as compared to initially resectable tumor patients, most likely reflecting a more extensive/aggressive surgical approach [41], rather than effects of neoadjuvant therapy. For the group of patients who present with locally advanced/unresectable disease, the median survival is 6–11 mo [42],[43]. Similarly, in our analysis, patients initially diagnosed as unresectable who were not resected had a median survival of 10.2 mo. In contrast, the 33.2% resected patients of the initially non-resectable tumor patients had an estimated median survival of 20.5 mo, which is within the range of pancreatic cancer patients with primary resection and adjuvant therapy. Patients who respond to chemotherapy have a better prognosis than those who do not. Therefore, one can only speculate about the survival time in responding patients if they were not resected. However, the fact that this subgroup of responding patients has the same median survival as patients who underwent immediate resection suggests that the increase in survival time for these patients can probably be attributed to the better treatment (resection) and is not due to patient selection. In conclusion, a relevant proportion, i.e. approximately one third of patients initially staged as locally advanced/unresectable, can be successfully resected following neoadjuvant therapy with an estimated median survival within the range of initially resectable tumor patients (Figure 7). Response to Neoadjuvant Therapy For the whole study cohort the number of patients with complete response was 3.9% and partial response 29.1%. Thus, approximately one third of the patients demonstrate radiographic and/or histological response towards neoadjuvant therapy. These response rates are relatively higher compared to data from palliative chemotherapies (5.5%–14.5% response rate [3]), but similar to published reports on combination chemotherapy (26.8% response rate [44]). Stable disease was observed in 43.9% of the patients, but progressive disease was detected in 20.8%. Interestingly, the data did not differ much in the two groups of initially resectable and non-resectable tumor patients, suggesting similar tumor biology. Future trials will have to address response prediction to identify the approximately one fifth of patients who apparently have a different (more aggressive) tumor biology. Interestingly, an analysis of trials with respect to monotherapy versus combination chemotherapy revealed higher complete and partial response rates in the combination therapy group. Higher response rates, however, did not translate into higher resection rates in the group of initially resectable tumor patients for mono- versus combination therapy. In contrast, the combination therapy resulted in an estimated 20% increase in the resection rate for initially non-resectable tumor patients. Inherently, a review based on retrospective and prospective phase I–II trials, cohort studies, and case series has several drawbacks: Statistical considerations Since no data from controlled randomized trials were existent, comparison of subgroups could solely be performed in a descriptive way. Although confidence limits were reported for point estimates of primary interesting proportions (frequency of exploration and/or resection), no effect sizes allowing for direct group comparisons were calculable. By estimating median survival times of study populations, two critical assumptions had to be made: a constant (time-independent) hazard rate and a similar underlying mechanism of patient drop-out (censoring (rates) due to lost follow-up or competing risks) within the trials. Further, no limits of confidence could be provided for estimated median survival times, and thus the presented estimates of median have to be cautiously interpreted as crude estimates of central tendency. Estimates of 1- and 2-y survival were provided as weighted averages. In this term, the total number of study patients was used for weighting because no sufficient information about patients at risk was available. These estimates again assume similar censoring rates within the studies. Further, because several studies had to be used for estimation of survival probabilities, differences between these estimates do not necessarily reflect the real change of survived individuals within one and the same population about time. Frequencies of resection and exploration showed a high heterogeneity (I2 values>80%; see below) between the trials. Consequently, although conservative random effect models were used throughout for calculation, point estimates may not reflect underlying latent varieties between the trials and may rather be an artificial average and therefore confidence intervals have to be particularly considered for interpretation. Heterogeneity Dealing with heterogeneity among study results is one of the most important challenges in meta-analysis. This problem can be partly overcome by the use of random effect models which consider within-study and between-study variability, as well as by stratified analysis of homogeneous study subgroups. Further, meta-regression analyses can be used for explanation of heterogeneity in terms of study-level covariates. In this analysis we have used random effect models and carried out meta-regression analyses to assess sources of heterogeneity. Institutions constituted an important source of heterogeneity in our analysis, underscoring the role of individual (center-specific) approaches/therapy algorithms even in high volume centers of pancreatic surgery that are thought to have comparable outcome parameters [4]. The age of the patients as well as the study period were identified as important variables for heterogeneity especially for perioperative morbidity and in-hospital mortality. Interestingly, differences in the study design (e.g. phase I–II clinical trials, case series, retrospective, prospective studies) had only minor impact on the variability of resection/exploration rates but were an important source of heterogeneity for response evaluation and morbidity. Overlapping patient populations There were 73 studies from the 17 centers that published more than 1 report with probably partially overlapping patient populations. Some patients might have been included, e.g. in a prospective analysis, later in a comparative analysis or in a retrospective study. Thus, there was the risk of producing artificially precise estimates since the same data were potentially tested multiple times (double counting). However, since the overlapping studies often analyzed different outcome parameters (e.g. toxicity evaluation, pathological response evaluation, etc.), we assumed this risk minor and opted to include these partially overlapping studies. Second, since a large number of outcomes were tested for the same population (multiplicity), there was the risk of false estimates for some of these outcomes. However, since only some studies overlapped, and mostly only by a subset of their populations, we assumed the risk of multiplicity moderate. Definition of resectability Resectability criteria and especially definitions of borderline resectable/unresectable tumors were variable. Thus, in more than 50% of the studies resectability criteria were not or not clearly stated, thereby constituting a potential source of bias. To minimize these effects we grouped borderline resectable and unresectable tumors together (termed non-resectable tumors), since the definition of resectable tumors is more reliable than the differentiation of borderline resectable and unresectable. Conclusion The present analysis provides the most comprehensive review regarding neoadjuvant therapies in resectable and non-resectable pancreatic cancers to date—thus, the best actual available evidence for response rates, treatment toxicities, resection rates, morbidity and mortality, and survival estimates. The most important findings are that in the group of resectable tumor patients, resection and survival rates after neoadjuvant therapy are similar to the ones observed in primarily resected tumor that are treated by adjuvant therapy. Thus, in this group of patients, the current data do not point to an obvious advantage of neoadjuvant therapy. In contrast, in patients initially staged locally advanced/unresectable, approximately one third of the patients can be resected following neoadjuvant therapy with comparable survival rates as patients who were staged as resectable before treatment. Due to the heterogeneity of applied protocols, data regarding the optimal chemotherapeutic and radiotherapeutic regimen cannot be extrapolated; however, the data suggest that combination chemotherapies result in higher response rates, which is reflected by higher resection rates at least in the group of initially non-resectable tumor patients. Future trials have first to clearly establish the role of neoadjuvant therapy specifically in locally advanced/unresectable tumors and subsequently to define optimal treatment protocols. In addition, common definitions for resectability/non-resectability as well as for response evaluation should be applied. As of now, the available data strongly suggest that patients with locally advanced/unresectable tumors should be included in neoadjuvant protocols and subsequently be re-evaluated for resection, which is possible in a relevant number of patients. Supporting Information Figure S1 PRISMA flow diagram. (0.07 MB DOC) Click here for additional data file. Table S1 Summary of the analyzed trials. (0.60 MB DOC) Click here for additional data file. Table S2 Currently ongoing/recruiting trials for resectable or non-resectable but non-metastatic PDAC. (0.07 MB DOC) Click here for additional data file. Text S1 PRISMA checklist. (0.07 MB DOC) Click here for additional data file. Text S2 Review protocol. (0.04 MB DOC) Click here for additional data file.
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          Adjuvant chemotherapy with gemcitabine and long-term outcomes among patients with resected pancreatic cancer: the CONKO-001 randomized trial.

          The prognosis for patients with pancreatic cancer is poor, even after resection with curative intent. Gemcitabine-based chemotherapy is standard treatment for advanced pancreatic cancer, but its effect on survival in the adjuvant setting has not been demonstrated. To analyze whether previously reported improvement in disease-free survival with adjuvant gemcitabine therapy translates into improved overall survival. CONKO-001 (Charité Onkologie 001), a multicenter, open-label, phase 3 randomized trial to evaluate the efficacy and toxicity of gemcitabine in patients with pancreatic cancer after complete tumor resection. Patients with macroscopically completely removed pancreatic cancer entered the study between July 1998 and December 2004 in 88 hospitals in Germany and Austria. Follow-up ended in September 2012. After stratification for tumor stage, nodal status, and resection status, patients were randomly assigned to either adjuvant gemcitabine treatment (1g/m2 d 1, 8, 15, q 4 weeks) for 6 months or to observation alone. The primary end point was disease-free survival. Secondary end points included treatment safety and overall survival, with overall survival defined as the time from date of randomization to death. Patients lost to follow-up were censored on the date of their last follow-up. A total of 368 patients were randomized, and 354 were eligible for intention-to-treat-analysis. By September 2012, 308 patients (87.0% [95% CI, 83.1%-90.1%]) had relapsed and 316 patients (89.3% [95% CI, 85.6%-92.1%]) had died. The median follow-up time was 136 months. The median disease-free survival was 13.4 (95% CI, 11.6-15.3) months in the treatment group compared with 6.7 (95% CI, 6.0-7.5) months in the observation group (hazard ratio, 0.55 [95% CI, 0.44-0.69]; P < .001). Patients randomized to adjuvant gemcitabine treatment had prolonged overall survival compared with those randomized to observation alone (hazard ratio, 0.76 [95% CI, 0.61-0.95]; P = .01), with 5-year overall survival of 20.7% (95% CI, 14.7%-26.6%) vs 10.4% (95% CI, 5.9%-15.0%), respectively, and 10-year overall survival of 12.2% (95% CI, 7.3%-17.2%) vs 7.7% (95% CI, 3.6%-11.8%). Among patients with macroscopic complete removal of pancreatic cancer, the use of adjuvant gemcitabine for 6 months compared with observation alone resulted in increased overall survival as well as disease-free survival. These findings provide strong support for the use of gemcitabine in this setting. Identifier: ISRCTN34802808.

            Author and article information

            [1 ]Department of Radiology, G.B. Rossi Hospital, University of Verona, 37134 Verona, Italy; ale.beleu@ (A.B.); giulioriz11@ (G.R.); (N.B.)
            [2 ]Department of Radiology, Istituto Oncologico Giovanni Paolo II, 70124 Bari, Italy; acalabrese22@
            [3 ]Department of Pathology, G.B. Rossi Hospital, University of Verona, 37134 Verona, Italy; paolacapelli@ (P.C.); aldo.scarpa@ (A.S.)
            [4 ]Department of Radiology, G. Martino Hospital, University of Messina, 98125 Messina, Italy; simona.caloggero@
            [5 ]Department of Radiology, Ospedale Generale Regionale “F. Miulli”, 70021 Acquaviva della Fonti, Italy; calbi.roberto@
            [6 ]Department of Radiology, Ospedale P. Pederzoli, 37019 Peschiera del Garda, Italy; paolo.tinazzimartini@
            [7 ]Department of Radiology, Ospedale Civile Maggiore Borgo Trento, Azienda Ospedaliera Universitaria Integrata, 37134 Verona, Italy; riccardo.derobertislombardi@
            [8 ]Department of Radiology, Ospedale “Sacro Cuore, Don Calabria”, 37024 Negrar, Italy; giovanni.carbogni@
            [9 ]Department of Surgery, G.B. Rossi Hospital, University of Verona, 37134 Verona, Italy; giovanni.marchegiani@ (G.M.); roberto.salvia@ (R.S.); claudio.bassi@ (C.B.)
            Author notes
            [* ]Correspondence: mirko.donofrio@ ; Tel.: +39-045-812-4301; Fax: +39-045-802-7490
            Cancers (Basel)
            Cancers (Basel)
            25 February 2019
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            © 2019 by the authors.

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