| Abstract|| |
Background/Aim: To construct quantitative prognostic models for colorectal cancer (CRC) based on COX-2/C-MET/KRAS expression status in clinical practice.
Patients and Methods: Clinical factors and COX-2/C-MET/KRAS expression status of 578 eligible patients from two Chinese hospitals were included. The patients were randomly allocated into training and validation datasets. We created several models using Cox proportional hazard models: SignatureC contained clinical factors, SignatureG contained COX-2/C-MET/KRAS expression status, and SignatureCG contained both. After comparing their accuracy, nomograms for progression-free survival (PFS) and overall survival (OS) were built for the best signatures, with their concordance index and calibration tested. Further, patients were subgrouped by the median of the best signatures, and survival differences between the subgroups were compared.
Results: For PFS, among the three signatures, SignaturePFS-CG had the best area under the curve (AUC), with the 1-, 2- and 3-year AUCs being 0.70, 0.73 and 0.89 in the training dataset, respectively and 0.67, 0.73 and 0.87 in the validation dataset, respectively. For OS, the AUCs of SignatureOS-CG for 1-, 2- and 3-years were 0.63, 0.71 and 0.81 in the training dataset, respectively and 0.68, 0.71 and 0.76 in validation dataset, respectively. The nomograms based on SignaturePFS-CG and SignatureOS-CG had good calibrations. Subsequent stratification analysis demonstrated that the subgroups were significantly different for both PFS (training:P < 0.001; validation:P< 0.001) and OS (training:P < 0.001; validation:P < 0.001).
Conclusions: Combining clinical factors and COX-2/C-MET/KRAS expression status, our models provided accurate prognostic information in CRC. They can be used to aid treatment decisions in clinical practice.
Keywords: C-MET, colorectal cancer, COX-2, KRAS, prognosis
|How to cite this URL:|
Liu J, Huang C, Wang J, Huang L, Chen S. COX-2/C-MET/KRAS status-based prognostic nomogram for colorectal cancer: A multicenter cohort study. Saudi J Gastroenterol [Epub ahead of print] [cited 2019 Apr 25]. Available from: http://www.saudijgastro.com/preprintarticle.asp?id=251382
Jianhua Liu and Chengzhi Huang contributed to the work equally
| Introduction|| |
Colorectal cancer (CRC) is one of the most common cancers worldwide, with an incidence ranking 3rd and 2nd in males and females, respectively, and a mortality rate ranking 4th and 3rd, respectively. To provide reasonable and effective treatment for patients, we need to have accurate prognoses for patients. Many studies have focused on this issue.,, However, most of them were qualitative rather than quantitative studies, meaning patients were divided into subgroups with high or low risks. Although this approach aided the identification of patients at risks for a specific patient, it provided limited information for their survival rate at a fixed time. Thus, these studies have not been able to aid doctors in making reasonable choices between aggressive and conservative treatment.
Apart from traditional clinical factors, genomic data may also be informative, especially when several genetic mutations are assessed in combination. To date, mutations resulting in the overexpression of COX-2, C-MET and KRAS, the key gene abnormalities in CRC, have been shown to have utility in CRC prognosis. According to a variety of studies, COX-2 overexpression is an adverse predictor for disease-specific survival in CRC.,, Mesenchymal-epithelial transition factor (C-MET) overexpression has also been shown to be closely correlated with CRC progression and metastasis and may interfere with anti-epidermal growth factor receptor (EGFR) strategies., Moreover, as a driver mutation and the principle aspect of somatic changes in CRC, KRAS mutations contribute to cell invasion and apoptosis suppression during tumor progression, along with resistance to anti-EGFR therapy.,, Therefore, a prognostic model combining mutations in these three genes status and clinical factors may be helpful not only for the current therapeutic regimens but also for future applications of targeted therapies.
Thus, we conducted this study in a multi-center cohort to develop a COX-2/C-MET/KRAS abnormalities expression-based prognostic nomogram for survival in CRC.
| Patients and Methods|| |
This multi-center study initially included 683 patients diagnosed with CRC at Guangdong General Hospital and Sun Yat-sen Memorial Hospital, between November 2010 and October 2014. After screening, 578 eligible patients were randomized using the R sample function with a 3:2 ratio to create a training dataset (346 cases) and a validation dataset (232 cases). The inclusion criteria were that the patient had (1) baseline characteristics recorded, including radiological examination and necessary laboratory tests; (2) at least one radiological progressive disease (PD) (confirmed by computed tomography [CT]/ magnetic resonance imaging [MRI]) or death confirmed, or had a follow-up >36 months before the cut-off date; and (3) the status of COX-2/C-MET/KRAS was confirmed at diagnosis. The exclusion criteria were (1) irregular follow-up and (2) the presence of other cancers. The inclusion and exclusion flowchart is shown in [Figure 1].
This study was approved by the Ethics Committee of Guangdong General Hospital and Sun Yat-sen Memorial Hospital. Informed consent was waived in lieu of the retrospective design of the study. In addition, before the analyses, all patients' information was anonymized and de-identified.
Treatments and follow-ups
Patient treatments were decided according to established guidelines., In general, radical surgery was prioritized for participants with stage I disease, and complete surgical excision with adjuvant 5-fluorouracil-based chemotherapy was used for stage II and III cases. Regarding patients with advanced CRC, chemotherapy alone or chemotherapy combined with targeted therapy [anti-vascular endothelial growth factor monoclonal antibody for all patients and anti-EGFR antibodies for patients with the absence of KRAS or BRAF mutations] were alternatives. The follow-up interval was 4–6 weeks, with chest X-rays, abdominal CT/MRI, and necessary laboratory tests. In addition, all suspected new lesions were confirmed by CT/MR.
Determination of COX-2/C-MET/KRAS expression status
The 578 formalin-fixed paraffin-embedded (FFPE) primary CRC samples, which were obtained from surgical/endoscopic biopsies were cut into 4-μm thick sections longitudinally, and the COX-2 and C-MET proteins were detected using a standard immunohistochemistry protocol. Briefly, after dewaxing, re-hydrating and antigen-retrieving, the sections were inhibited for endogenous peroxidase activity and for blocked nonspecific antibody binding, followed by incubation with primary antibody against COX-2 (BD, NJ, USA; lyophilized, 1:200 dilution) or C-MET (BD; lyophilized, 1:100 dilution) overnight at 4°C. Subsequently, slides were incubated with secondary antibodies for 30 min; then, the immunoreaction was visualized with the streptavidin-biotin peroxidase complex method. Finally, the sections were visualized using an optical microscope (CX31; Olympus Corporation, Tokyo, Japan). The findings were judged by two independent pathologists, and COX-2 or C-MET staining was analyzed by multiplying the percentage of positive cells (P) by staining intensity (I). Briefly, P was defined as 0, 1, 2 or 3 score when P accounted for <5%, between 5% and 25%, between 26% and 50%, or >50% of total cells, respectively. I was scored 0 for absent/weak staining, 1 for moderate staining, and 2 for strong staining. Thus, the total scores ranged from 0 to 6, and overexpression was defined as a score of 6.
KRAS mutations were analyzed for each FFPE specimen using polymerase chain reaction (PCR)-based direct gene sequencing. Genomic deoxyribonucleic acid (DNA) was extracted with QIAamp DNA FFPE Tissue Kit Qiagen (Hilden, Germany) in accordance with the manufacturer's protocol, and cancer cell rich regions were ascertained beforehand using the application of hematoxylin and eosin (H and E) staining to ensure that all cases tested for enrichment of ≥70% tumor cells. Subsequently, DNA concentration was measured using an ND-1000 spectrophotometer (Thermo Scientific, Wilmington, DE, USA), and KRAS mutations (including exons 2, 3, and 4) of all tumor samples were determined. Primer pairs for gene amplifications were designed with AmpliSeq Designer software, version 1.2.6 software (Life Technologies). DNA amplification was carried out with GoTaq® Hot Start Polymerase (Promega, Madison, WI, USA) and 0.2 μM of each primer using the GeneAmp PCR System 9700 (Applied Biosystems, Foster City, CA, USA). Cycling conditions were as described previously. After identification by agarose gel electrophoresis, the PCR products were purified with the DNA Clean/Extraction Kit (GeneMark), then submitted to direct sequencing on an ABI 3730xl genetic analyzer (Invitrogen Life Technologies, Carlsbad, CA, USA), and detailed steps were consistent with those reported earlier. The resulting reads were aligned using Chromas software, and all mutations were confirmed in both the sense and anti-sense directions.
Clinical factors included sex (classified as male or female), age (classified as ≤60 or >60 years), tumor location (classified as right colon or left colon/rectum), differentiation (classified as moderate/well or poor), TNM stage (classified as I, II, III, or IV), T stage (classified as T1/T2 or T3/T4), N stage (classified as N0, N1 or N2), M stage (classified as M0 or M1), carcinoembryonic antigen (CEA) (classified as <20 ng/mL or >20 ng/mL), KRAS (classified as mutation and wild-type), COX-2 (classified as low expression or overexpression), and C-MET (classified as low expression or overexpression). We assumed that T, N and M had different prognostic values, so we included both TNM stage as a comprehensive factor and T, N and M as separate factors. Because treatments were decided according to TNM stage, treatment was not included in the model construction to avoid the influence of collinearity.
Compared with progression-free survival (PFS), overall survival (OS) may be influenced more by confounding factors, so we used PFS as our primary outcome along with OS as our secondary outcome. PFS and OS were determined by the time span from enrollment start time to PD/censoring and death/censoring, respectively. PD was defined in accordance with Response Evaluation Criteria in Solid Tumors (RECIST 1.1).
Categorical variables expressed as percentages were compared by the Pearson's χ2 test or the Fisher's exact test (when the expected frequency was less than 5) as appropriate. PFS and OS were compared using the logrank test.
For the general process of model construction, to test the prognostic value of COX-2/C-MET/KRAS for PFS and OS, we first randomly separated the cohort into training and validation sets. Second, we performed the analysis for PFS and OS seperately. In general, signatures were built using clinical factors (SignaturePFS-C and SignatureOS-C), gene expression/mutation abnormalities (SignaturePFS-G and SignatureOS-G) and both (SignaturePFS-CG and SignatureOS-CG). All candidate predictors were included in the development of the prediction models. The two types of variables (clinical factors and DNA mutations) separately entered SignatureC and SignatureG. All the factors identified above were then introduced into SignatureCG using the backward stepwise COX-2 proportional hazard model by Akaike information criterion. Third, for 1-, 2- and 3-year PFS and OS, likelihood ratio tests were used to compare the different models. In addition, for 1-, 2- and 3-year PFS and OS, we estimated the area under curve (AUC) of the three signatures using the approach of Heagerty et al., and a nomogram was constructed for the optimal signatures with their calibration tested to compare the expected and observed survival probabilities. Finally, split-sample validation of the prediction model was conducted to assess the stability of the model. The patients were subgrouped by the median of the optimal signatures, the Kaplan-Meier method was used to estimate the survival function, and the logrank test was used to compare survival.
All statistical tests performed were two-sided, and P values less than 0.05 were considered as statistically significant. Data was analyzed by the R statistical package (http://www.r-project.org/).
| Results|| |
Patients' baseline characteristics
After random allocation into the two groups, the number of patients in the training and validation datasets were 346 and 232, respectively. In the total study population, 258 cases had cancer located in the right colon (training: 149; validation: 109), and 320 had cancer located in the left colon or rectum (training: 197; validation: 123). By the end date of follow-up, 411 PD occurred (training: 248; validation: 163), and 337 cases died (training: 200; validation: 137). Their characteristics are shown in [Table 1] and [Table 2].
|Table 1: Baseline demographics and characteristics of training and validation dataset (I)|
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|Table 2: Baseline demographics and characteristics of training and validation dataset (II)|
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Gene expression status
For all participants, 456 cases COX-2 overexpression (training: 266; validation: 190), 381 was C-MET overexpression (training: 239; validation: 142) [Figure S1 [Additional file 1]], and 216 cases exhibited KRAS mutations (training: 123; validation: 93). A total of 326 patients had overexpression for both COX-2+C-MET (training: 212; validation: 114), 176 had both COX-2+KRAS abnormalities (training: 92; validation: 86), 180 had abnormalities of both C-MET+KRAS (training: 114; validation: 66), and 132 had abnormalities of all three (training: 86; validation: 46). However, there was no statistical difference between the training and validation datasets.
Results of univariate and multivariate analyses are shown in [Table S1 [Additional file 4]] and [Table S2 [Additional file 5]]. Considering the prognostic effects of COX-2 and C-MET,,, although they were not statistically different in the multivariate analysis of PFS [Table S1] and [Table S3 [Additional file 6]], we still tested whether the integration of COX-2 and C-MET improved the models. The results showed that for SignaturePFS-CG, adding information of COX-2 and C-MET expression increased the AUC of 3-year PFS in the validation dataset (0.87 vs. 0.84, [Figure 2] and [Figure S2 [Additional file 2]]. Thus, although calibration between the nomograms were similar [Figure S3 [Additional file 3]], we believed it was reasonable to add COX-2 and C-MET expression into the nomogram for SignaturePFS-CG. Finally, the formulas were as follows: PFS (with COX-2 and C-MET): points = 23 × (age > 60) +26 × (tumor location in the left colon and rectum) +37 × (N stage = N1) +78 × (N stage = N2) + 100 × (M stage = M1) + 29 × (CEA ≥ 20 ng/mL) + 49 × (KRAS mutation) + 14 × (COX-2 overexpression) + 2 × (C-MET overexpression); PFS (without COX-2 and C-MET): points = 25 × (age > 60) + 27 × (tumor location in the left colon and rectum) + 36 × (N stage = N1) + 75 × (N stage = N2) + 100 × (M stage = M1) + 30 × (CEA ≥ 20 ng/mL) + 40 × (KRAS mutation); OS: points = 41 × (age > 60) + 35 × (N stage = N1) + 64 × (N stage = N2) + 100 × (M stage = M1) + 39 × (CEA ≥ 20 ng/mL) + 55 × (KRAS mutation).
|Figure 2: Comparing the accuracy of progressioin-free survival (PFS) by the three signatures. For the 1-, 2-, and 3-year PFS, the AUC of SignaturePFS-C, SignaturePFS-G, and SignaturePFS-CG in the training dataset were 0.68, 0.60 and 0.70; 0.70, 0.65 and 0.73; and 0.83, 0.82 and 0.89. Those in the validation dataset were 0.67, 0.60 and 0.67; 0.73, 0.62 and 0.73; and 0.86, 0.78 and 0.87. In addition, SignaturePFS-CG has the highest accuracy in both datasets. AUC: Area under the curve; C: Clinical factors; G: Gene abnormalities; CG: Clinical factors plus gene abnormalities|
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For PFS, among the three signatures (SignaturePFS-C, SignaturePFS-G, and SignaturePFS-CG), the AUCs in training dataset were 0.68, 0.60 and 0.70 for 1 year; 0.70, 0.65 and 0.73 for 2 years; and 0.83, 0.82 and 0.89 for 3 years [Figure 2], respectively, with SignaturePFS-CG having the best performance [Table 3]. In the validation dataset, the AUCs were 0.67, 0.60 and 0.67 for 1 year; 0.73, 0.62 and 0.73 for 2 years; and 0.86, 0.78 and 0.87 for 3 years [Figure 2], respectively, and SignaturePFS-CG also had the best performance [Table 3].
|Table 3: Pairwise comparison among signatures by Likelihood ratio tests (P-value)|
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For OS, among the three signatures (SignatureOS-C, SignatureOS-G and SignatureOS-CG) the AUCs in the training dataset were 0.61, 0.57 and 0.63 for 1 year; 0.67, 0.61 and 0.71 for 2 years; and 0.72, 0.76 and 0.81 for 3 years [Figure 3], respectively, with SignatureOS-CG achieving the best performance [Table 3]. In the validation dataset, the AUCs were 0.64, 0.62 and 0.68 for 1 year; 0.70, 0.63 and 0.71 for 2 years; and 0.77, 0.61 and 0.76 for 3 years [Figure 3], respectively. Although SignatureOS-CG had the best performance for 1 and 2-year OS, it was inferior to SignatureOS-C for 3-year OS [Table 3].
|Figure 3: Comparing the accuracy of overall survival (OS) by the three signatures. For the 1-, 2- and 3-year OS, the AUC of SignatureOS-C, SignatureOS-G, and SignatureOS-CG in the training dataset were 0.61, 0.57 and 0.63; 0.67, 0.61 and 0.71; and 0.72, 0.76 and 0.81. SignatureOS-CG has the highest accuracy. Those in the validation dataset were 0.64, 0.62 and 0.68; 0.70, 0.63 and 0.71; and 0.77, 0.61 and 0.76. SignaturePFS-CG has the highest accuracy in the 1- and 2-year, but for 3-year, SignaturePFS-C was a little better. AUC: Area under the curve; PFS: Progression-free survival; C: Clinical factors; G: Gene abnormalities; CG: Clinical factors and gene abnormalities|
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From these results, nomograms based on SignaturePFS-CG were constructed for PFS [Figure 4]a and achieved good calibration in both the training [Figure 4]b and validation [Figure 4]c datasets. For OS, a nomogram was also constructed [Figure 4]d, with good calibration in both datasets [Figure 4]e, [Figure 4]f.
|Figure 4: Nomogram and calibration based on SignaturePFS-CG and SignatureOS-CG. For PFS, the nomogram based on SignaturePFS-CG (a) has good calibration, both in training (b) and validation (c) datasets. For OS, the nomogram based on SignatureOS-CG (d) also has good calibration, both in training (e) and validation (f) datasets. AUC: Area under the curve; PFS: Progression-free survival; OS: Overall survival; C: Clinical factors; G: Gene abnormalities; CG: Clinical factors and gene abnormalities|
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Kaplan-Meier survival analysis
When divided by the median of SignaturePFS-CG (threshold: 0.0640), the two groups had a statistically significant difference for PFS, both in the training (P < 0.001, [Table 4] and [Figure 5]a and validation (P < 0.001, [Table 4] and [Figure 5]b datasets. Similar results were observed for OS when patients were separated by the median of SignatureOS-CG (threshold: 0.1969; training: P <0.001; and validation: P <0.001; [Table 4] and [Figure 5]c, [Figure 5]d.
|Figure 5: Signatures based subgroup Kaplan-Meier analysis. Separated by the median of SignaturePFS-CG at 0.0640, the two subgroups have significant statistical difference in PFS, both for training (a) and validation (b) datasets. Separated by the median of SignatureOS-CG at 0.1969, similar results were observed in training (c) and validation (d) datasets. PFS: Progression-free survival; OS: Overall survival; C: Clinical factors; G: Gene abnormalities; CG: Clinical factors and gene abnormalities|
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| Discussion|| |
Due to the nature of its clinical heterogeneity and aggressiveness, CRC presents with a high incidence of distant metastasis and accompanying poor prognosis. During the progression from uncontrolled cell growth to invasive cancer, a series of clinical and genetic abnormalities as well as deregulation in cellular homeostasis are involved. At present, many genes have been studied in CRC, with COX-2/C-MET/KRAS being the most representative. Up-regulation of COX-2 and C-MET as well as KRAS mutations play pivotal roles in accelerating cancer-promoting activity and worsening prognosis. To select more individualized treatments for patients, accurate prognostic models should be constructed including both clinical factors and genetic information. In this study, we constructed COX-2/C-MET/KRAS expression-based prognostic models in a multicenter cohort of patients. The signatures were accurate in both the training and validation datasets, especially for long-term survival (3-year PFS and OS). In addition, the nomograms based on them also showed good calibration for 1-, 2- and 3-year PFS and OS. Furthermore, when divided by the median of the signatures, patients with low and high risk for CRC could be identified.
CRC progression is a multi-step process that includes various genetic events involving dysregulation of metastasis-associated genes and inactivation of tumor repressor genes. Recently, a variety of studies have contributed to the development of CRC prognostic models, demonstrating that the abnormalities of clinical and genetic features might be significant predictors for poor clinical outome.,, However, there are limitations to the application of these conclusions. First, fragmented processes identifying informative factors can only qualitatively identify patients at risk but are without comprehensive integration of prognostic factors, so quantitative survival prediction remains a challenge. Second, models should be validated in independent datasets to show that the conclusions could be applied beyond the original cohorts. Third, to facilitate clinical application, the factors included in the models should be easily collected during diagnosis and treatment. With similar accuracy, the fewer additional examinations that need to be performed, the more convenient the models might be. From these issues, we chose the three most widely tested genes in clinical practice (expression of COX-2, C-MET and KRAS mutation status) and combined them into an integral signature with testing in both training and validation datasets. The accuracy of our models was comparable to a previous study, especially for the 3-year PFS. However, we used fewer genes (3 vs. 13), which are widely tested in CRC management, so our model may be more convenient for clinical practice. In addition, we constructed models not only for PFS but also for OS.
In addition, our results indicated that some prognostic factors were common for both PFS and OS, such as age, N stage, M stage, CEA level and KRAS status. However, tumor location and the expression levels of COX-2 and C-MET were only informative for PFS. These data may have suggested that N and M stages were more important than T stage because cases with metastases in lymph nodes or beyond the primary site were more aggressive and more difficult to control by current therapeutic approaches. In addition, tumor location might influence the short-term clinical response to anti-tumor therapies, especially for chemotherapy. Third, a high expression of both COX-2 and C-MET had synergistic effects in regulating the malignant behavior of CRC, and these proteins are important markers for invasion and metastasis as well as potential molecular targets for specific treatments., In addition, OS is the consequence of multiple effects, not only including therapeutic options but also the natural behaviors of the tumor. Thus, KRAS status was informative for both PFS and OS. Notably, KRAS mutation has been shown to be associated with resistance to anti-EGFR therapies, and influences the response of some CRC patients to targeted medicine.
However, there were some limitations in our study. First, because we did not have PD or death information within 2-years of follow-up for many patients, the AUCs of 1- and 2-year PFS and OS were less accurate compared with those for 3-years. Second, because of the retrospective nature of our study, multiple confounding factors likely existed after PD that affected OS, and as such subtle inconsistencies were found regarding the AUC comparison between the training and validation models, in which SignatureOS-CG was the most accurate in the training dataset but was slightly inferior in the validation dataset. Third, considering racial and regional differences, whether our results could be applied for Western patients requires further exploration. Fourth, other factors such as Plastin3, SPC18 and PTEN,, may also have contributed to CRC survival, and with improvements in testing methods and interpretion of these genes, we might be able to use them to improve the performance of our models. All of these aspects necessitate future study with a larger cohort, especially with prospective data.
In conclusion, we developed abnormal COX-2/C-MET/KRAS expression-based prognostic models for both PFS and OS and verified their accuracy in both training and validation datasets. We concluded that with proper integration, combining these three genes with clinical factors provided more prognostic information for CRC and may facilitate individualized treatment decision-making in the future.
This work was supported by a grant from the Science and Technology Program of Guangzhou, China (grant no. 201804010426).
Financial support and sponsorship
This work was supported by a grant from the Science and Technology Program of Guangzhou, China (grant no. 201804010426).
Conflicts of interest
There are no conflicts of interest.
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Department of Oncology, Cancer Center, Guangdong General Hospital, Guangdong Academy of Medical Sciences, 123 Huifu Road West, Guangzhou 510180
Source of Support: None, Conflict of Interest: None
[Figure 1], [Figure 2], [Figure 3], [Figure 4], [Figure 5]
[Table 1], [Table 2], [Table 3], [Table 4]