PDF
Citation
Print
Introduction
Hepatocellular carcinoma (HCC) is the sixth most common cancer and the third leading cause of cancer-related death worldwide [1]. Surgical resection is recognized as one of the most important curative treatments. But the high post-resection recurrence rate of approximately 70% threatens the long-term survival of HCC patients [2,3]. Current staging systems such as Barcelona Clinic Liver Cancer (BCLC) and 7th American Joint Committee on Cancer (AJCC) cannot accurately predict recurrence and survival, because the individual prognosis is affected by various risk factors including patients’ general condition and their tumor characteristics whereas these systems only considered limited variables. Therefore, it is meaningful to come up with an improved tool that can perform individualised evaluation of postoperative recurrence and survival by enrolling potential risk factors. With this tool, clinicians can identify surgical patients with poor survival at the earliest stage and consequently perform additional interventions to prohibit or delay the recurrence and prolong life expectancy.
Annually, China contributes to almost half of new HCC cases in the world, and a majority of these HCCs are developed with an underlying chronic hepatitis B virus (HBV) infection [4]. Several recent studies have revealed the significant association between chronic inflammatory diseases and higher incidence of malignant cancers including HCC [5-7]. In this regard, given that HBV-related HCC is developed in the inflammatory microenvironment, it is reasonable to correlate with systemic inflammation [6,7]. Inflammatory hematological or biochemical components such as monocyte, neutrophil, or lymphocyte have been used to reflect tumor status via various combinations entitled as inflammation-related markers [8,9]. Emerging evidences suggested that preoperative peripheral inflammatory indices might be capable of predicting the prognosis of HCC patients, including neutrophil to lymphocyte ratio (NLR) [9], platelet to lymphocyte ratio (PLR) [10], lymphocyte to monocyte ratio (LMR) [11], gamma-glutamyl transpeptidase to platelet ratio (GPR) [12], prognostic nutritional index (PNI) and systemic immuneinflammation index (SII) [13,14]. Besides, aspartate aminotransferase (AST) also plays an important role in evaluating the level of inflammation-induced liver injury and correlates with HCC mortality, so AST-related inflammatory markers such as AST to platelet ratio index (APRI) [15], AST to neutrophil ratio index (ANRI) [16], and AST to lymphocyte ratio index (ALRI) [14] were also reported.
However, most previous studies only investigated one or two of these inflammatory markers at one time [9-18], which are insufficient to predict prognosis considering the heterogeneous nature of HCC and its complicated microenvironment. Besides, studies focusing on HBV-related HCC were rare. Therefore, a comprehensive and applicable model by incorporating available inflammatory markers of prognostic significance with other potential prognostic factors would be valuable for HCC patients with chronic HBV hepatitis infection who underwent hepatectomy. Nomogram refers to an easy-to-operate tool used to predict the survival outcomes of HCC patients [19-21]. The models were developed mainly using patient-, treatment-, and tumor-related features [19-22]. However, no predictive nomogram was built depending on the analysis of overall existed inflammation-related markers until now.
In this study, we recruited a large Chinese population to build and validate prognostic nomograms for HCC patients who underwent curative hepatectomy based on peripheral inflammation-related markers and accessible clinical parameters, to guide postoperative adjuvant interventions and follow-ups.
Materials and Methods
1. Study population
We retrospectively reviewed the medical records of all adult patients diagnosed with primary HCC who underwent curative resection as initial treatment at the First Affiliated Hospital of Sun Yat-sen University (FAHSYSU) and Sun Yatsen University Cancer Center (SYSUCC) from November 2003 through December 2015. The inclusion criteria were adopted as follows: (1) 18 years old and above; (2) HBV surface antigen (HBsAg) positive; (3) without preoperative treatment for HCC; (4) sufficient liver functional reserve: ChildPugh class A or B; (5) histologically proven HCC; (6) no history of other malignancies; and (7) absence of pathologic tumor-positive resection margins. The exclusion criteria were as follows: (1) HBV and other hepatitis virus co-infection; (2) combined HCC and cholangiocarcinoma; (3) incomplete clinical data; (4) lost to follow-up or insufficient follow-up time; and (5) radiologic evidence of extrahepatic metastasis. Among 1,244 patients received curative resection, 1,092 were with HBsAg positive. Two hundred and three patients were excluded due to the following reasons: age < 18 years (n=5), co-infected hepatitis (n=23), other malignancies (n=12), incomplete data (n=84), and insufficient follow-up time (n=79). Finally, 654 patients from FAHSYSU were enrolled in this study and randomly assigned into the training (n=457) and the internal validation (n=197) cohorts in a 7:3 ratio. An independent group of 235 patients from SYSUCC were designated as the external validation cohort. The workflow diagram of patient selection was shown in Fig. 1.
2. Data collection
The following clinical information was collected, including (1) preoperative patient characteristics (age, sex, leukocyte count, neutrophil ratio, monocyte ratio, lymphocyte ratio, haemoglobin, platelet, albumin, AST, alanine aminotransferase (ALT), gamma-glutamyl transpeptidase (GGT), total bilirubin (TBIL), prothrombin time (PT), international normalized ratio (INR), α-fetoprotein (AFP), Eastern Cooperative Oncology Group performance status, and Child-Pugh class); (2) tumor radiological features (tumor number, tumor diameter, macrovascular invasion, and BCLC stage); (3) resection factors (resection margin); and (4) pathological factors (Edmonson-Steiner tumor differentiation, cirrhosis, satellite lesions, microvascular invasion as well as tumor capsule).
3. Formulas of inflammation-related markers
Inflammation-related markers including NLR, PLR, LMR, GPR, APRI, ANRI, ALRI, SII, and PNI were taken within 14 days prior to surgery. Detailed formulas were shown in S1 Table.
4. Hepatic resection
Surgery (open hepatectomy, n=843; laparoscopic hepatectomy, n=46) was performed by surgeons have more than 10-year experience. The management guidelines for choosing open and laparoscopic liver resection were nearly the same. Intraoperative ultrasound was routinely used to detect the tumor burden, location, and invasion of tumor into blood vessels. Resection types composed of non-anatomic resection and anatomic resection and was chosen mainly depends on the current guidelines [23]. Non-anatomic resection refers to wedge resection and tumor enucleation. Anatomic resection refers to the resection of segment relied on Couinaud classification, which completely removed the targeted tumor and corresponding hepatic territory, commonly performed if patients have sufficient liver function. Hepatic parenchymal transection was performed by using a harmonic scalpel or a bipolar electrocautery. And in some cases, temporary hepatic inflow occlusion was used during this process. The thrombectomy for patients in BCLC stage C with tumor thrombus was performed following the procedure described in the study by Shi et al. [24]. Curative resection was defined as complete removal of tumor with a negative resection margin (R0 resection) confirmed by pathological examination.
5. Follow-ups
Contrast-enhanced ultrasound (CEUS) of the liver, contrast-enhanced computed tomography (CECT) of the abdomen and chest radiography were performed 4 weeks after the surgery to evaluate the treatment efficacy. Then the follow-up was performed every 3 months for the first 2 years, every 6 months from 2 to 5 years, and every 12 months thereafter. During each follow-up, CEUS and blood examinations including AFP and liver function relative parameters were performed. CECT or contrast-enhanced magnetic resonance imaging was carried out every 6 months.
The diagnosis of recurrence was relied on the evidence of imaging findings according to the current guidelines [25]. Once recurrence occurred, these patients would receive optimal treatment for recurrent lesions, depending on tumor and clinical characteristics. To avoid potential bias, those received liver transplantation after recurrence were excluded because of its strong impact on survival. Recurrence date was defined as the date of the new lesion firstly appeared on imaging examination. The recurrence-free survival (RFS) was calculated from the date of surgery to the date of recurrence or death or last follow-up, and overall survival (OS) was calculated from the date of surgery to the date of death or last follow-up. The study was censored on January 24, 2019.
6. Statistical analysis
Continuous variables were described as median and quartile range and compared using the independent sample t test or the Mann-Whitney U test. Categorical variables were described as frequency and percentage compared using chi-square test or Fisher exact test. Optimal cut-off points for inflammation-related markers and other continuous variables, except AFP and tumor diameter, were based on the primary outcome of RFS among all the patients from FAHSYSU, using the maximally selected rank statistics from “maxstat” R package.
All the patients from FAHSYSU were randomly divided into a training cohort and an internal validation cohort according to a 7:3 ratio. All the patients from SYSUCC entered the external validation cohort. LASSO with one standard error of lambda and then stepwise based on the Akaike information criterion were used to select the variables to construct a cox regression model in the training dataset. The nomograms were constructed to predict the survival rates based on the final cox model. The Cox model from the training cohort was fixed and applied into the two validation cohorts. The performance of the model was evaluated by Harrell's C-index, time-dependent receiver operating characteristic (ROC) curves and calibration curves in the three cohorts. Comparison of the C-indices between the nomogram and BCLC or 7th AJCC systems were performed with “compare C” R package. Survival curves were constructed using the Kaplan-Meier method and compared with the log-rank test. Statistical analyses were performed using R 3.4.3 (http://www.r-project.org) and Stata/MP 14.0. p-values less than 0.05 were considered statistically significant, and all tests were two-sided.
Results
1. Baseline characteristics
A total of 889 patients were recruited in this study. The baseline characteristics of patients in each cohort were summarized in Table 1. Among all patients, the mean tumor size was 6.8 cm, with 506 (56.9%) having tumor diameter larger than 5 cm. A large proportion of patients (n=682, 76.7%) were with solitary tumor. According to the BCLC staging system, more than half of the patients (60.6%) were classified into stage 0/A, 10.2% in stage B and the remaining (29.1%) within stage C. And most of the patients (96.0%) were with Child-Pugh liver function class A. There was no significant difference between the training and the internal validation cohorts, except for the ALT level. However, some characteristics in the external cohort such as peripheral parameters (platelet, haemoglobin, AST, GGT, PT, and INR), Child-Pugh score, tumor features (tumor stage, tumor number, tumor diameter, resection margin, and tumor differentiation), and most inflammation-related markers were significantly different compared to those in the training cohort (p < 0.05).
2. Survival outcomes
In the training cohort, the median follow-up was 38.2 months. The 1-, 2-, and 3-year RFS and OS rates were 51.31%, 41.80%, 37.11%, and 81.51%, 71.16%, 63.17%, respectively. In the internal and external validation cohorts, the median follow-up was 37.8 months and 45.8 months, respectively. The 1-, 2-, and 3-year RFS rates were 52.07%, 41.73%, and 37.55% in the internal cohort and 55.34%, 44.00%, 34.88% in the external cohort. The corresponding 1-, 2-, and 3-year OS rates were 79.32%, 68.82%, and 65.33% in the internal cohort and 91.10%, 81.36%, and 70.86% in the external cohort, respectively.
3. Univariate and multivariate analysis in the training cohort
Univariate and multivariate Cox regression analyses were performed in 457 patients from the training cohort for both RFS and OS. Results were shown in S2 Table. The optimal cut-off values of inflammation-related markers were determined as mentioned above (S3 Table). Finally, NLR, GPR, INR, microvascular invasion, satellite lesions, tumor number, tumor diameter, and macrovascular invasion were selected to build nomogram for RFS. GPR, TBIL, INR, AFP, microvascular invasion, satellite lesions, and tumor diameter as well as macrovascular invasion were used to build nomogram for OS. All of these variables were independent prognostic factors of RFS and OS (Tables 2 and 3).
4. Prognostic nomogram for RFS
Based on the eight significant prognostic factors (NLR, GPR, INR, microvascular invasion, satellite lesions, tumor number, tumor diameter, and macrovascular invasion) demonstrated in the multivariate analysis, a nomogram was established to predict 1-, 2-, and 3-year RFS rates of HBV-related HCC patients who underwent resection (Fig. 2A).
This model exhibited good efficacy in estimating postoperative recurrence with a higher C-index of 0.701 (95% confidence interval [CI], 0.669 to 0.732) in the training cohort, and 0.701 (95% CI, 0.647 to 0.755) and 0.707 (95% CI, 0.657 to 0.756) in the internal and external validation cohorts, respectively. The calibration curves for 1-, 2- and 3-year RFS rates in the training (A), internal validation (B), and external validation (C) cohorts were largely overlapped with its standard lines (Fig. 3). The predictive value of our nomograms for RFS were significantly higher than that of the BCLC staging system (0.629 [95% CI, 0.599 to 0.658], p < 0.001; 0.626 [95% CI, 0.579 to 0.673], p < 0.001; 0.599 [95% CI, 0.575 to 0.623], p < 0.001) and 7th AJCC system (0.620 [95% CI, 0.590 to 0.649], p < 0.001; 0.604 [95% CI, 0.558 to 0.650], p < 0.001; 0.600 [95% CI, 0.574 to 0.626], p < 0.001).
The area under the ROC curves (AUC) of the nomogram in predicting 1-, 2-, and 3-year RFS in the training cohort was 0.780, 0.761, and 0.755, respectively (Fig. 4A). In addition, the AUC of this nomogram in predicting 1-, 2-, and 3-year RFS was 0.781, 0.757, and 0.781 in the internal validation cohort and 0.766, 0.755, and 0.781 in the external validation cohort (Fig. 4B and C).
The model was capable of stratifying patients into three subgroups (low-, medium-, and high-risk groups) by their individual risk scores. In all the three cohorts, the RFS curves were broadly separated among these three subgroups of different risks (p < 0.001) with poorer survival in high-risk patients, which further indicated the good discriminatory ability of this prognostic model (Fig. 5A-C).
5. Prognostic nomogram for OS
The nomogram used to evaluate the probability of 1-, 2-, and 3-year OS was built on the following variants: GPR, TBIL, INR, AFP, microvascular invasion, satellite lesions, tumor diameter, and macrovascular invasion (Fig. 2B). The nomogram also revealed better performance in the training cohort with a higher C-index of 0.761 (95% CI, 0.728 to 0.795) than the BCLC criteria (0.665 [95% CI, 0.629 to 0.701], p < 0.001) and 7th AJCC system (0.652 [95% CI, 0.616 to 0.689], p < 0.001) did. The C-index value in the internal and external validation cohorts reached 0.706 (95% CI, 0.640 to 0.772) and 0.708 (95% CI, 0.646 to 0.771), respectively, which were also greater than the conventional BCLC staging system (0.636 [95% CI, 0.578 to 0.694], p < 0.01; 0.602 [95% CI, 0.567 to 0.637], p < 0.001) and 7th AJCC system (0.623 [95% CI, 0.567 to 0.680], p < 0.01; 0.596 [95% CI, 0.559 to 0.633], p < 0.001). As shown in the calibration plots, the calibration curves for 1-, 2-, and 3-year OS were all well-matched with the standard lines (Fig. 3D-F).
In this nomogram, the AUC of 1-, 2-, and 3-year OS in the training cohort was 0.822, 0.814, and 0.822, respectively (Fig. 4D). In addition, the AUC of this nomogram in predicting 1-, 2-, and 3-year OS was 0.789, 0.799, and 0.786 in the internal validation cohort and 0.838, 0.750, and 0.765 in the external validation cohort (Fig. 4E and F). Similar to RFS, patients were also classified into low-, medium- and high-risk subgroups according to scores derived from nomogram for OS. The OS rates were significantly different among the risk groups, with lower OS rate in the subgroup of higher risk of death (p < 0.001) (Fig. 5D-F).
Discussion
Our study constructed novel prognostic nomograms for HCC patients treated with surgery by combining inflammation-related markers and conventional risk parameters (tumor features and patient characteristics), and further validated them in an independent external cohort. The models showed better predictive performance than conventional BCLC and 7th AJCC staging systems. Moreover, our results suggested NLR and GPR were the two inflammation-related marker that independently associated with prognosis.
Emerging evidence demonstrated that inflammation status involved in the development of malignant cancers through promoting angiogenesis and inhibiting apoptosis [26]. Inflammatory markers made up by inflammation-related hematologic and biochemical factors have been created to reflect the status of systemic inflammation. While various markers were closely connected to the survival, it is of great potential to build inflammatory markers-based models to predict the prognosis of HCC patients [9-16,18]. Yet, it remains unknown which one had a relatively superior prognostic significance among these inflammatory markers, due to that few studies did the comparison. In this study, we did an overview analysis of the overall reported inflammation-related markers for the first time in a large Chinese population. Multivariate analysis identified that NLR and GPR were the independent prognostic factors for RFS of surgically treated HCC when all the reported inflammatory markers were enrolled into analysis. NLR was the firstly formed inflammation-based factor using to reflect the systemic inflammation response. It has been widely recommended as a potential predictor of survival in various malignancies [9]. GPR was initially introduced by Lemoine et al. [27] as an indicator with high accuracy for the degree of liver fibrosis and cirrhosis in patients with chronic HBV infection. As the presence of cirrhosis is a known risk factor for HCC, it can possibly explain why GPR could be used to evaluate the survival of HCC patients. Consistent with the result in Gomez et al.'s [9] and Wang et al.’s [12] studies, we found that NLR and GPR have superior capacity in predicting prognosis than other inflammation-related scores. Our results in OS also revealed that GPR has the highest prognostic value, and the higher GPR indicated a poorer survival. Although the molecular mechanism of NLR and GPR in HCC progression was unclear, they were still selected to establish our nomograms.
The prognosis of HCC cannot completely depend on inflammation, since patients’ general condition, pathological characteristics (microvascular invasion and satellite lesions) and tumor burden (tumor number, tumor diameter, and macrovascular invasion) have also been recognized as significant factors influencing survival [28,29]. Other variants included in the RFS nomogram were INR, microvascular invasion, satellite lesions, tumor number, tumor diameter, and macrovascularinvasion. Those included in the OS nomogram were TBIL, INR, AFP, microvascular invasion, satellite lesions, tumor diameter, and macrovascular invasion. These variants identified in multivariate analysis were independently correlated with prognosis. Conventional BCLC staging systems commonly used to classify HCC patients into different stages, provide optimal clinical management and corresponding survival outcomes [3]. However, it did not take the above important factors which have been stressed the value of prognosis in HCC, such as microvascular invasion, satellite lesions, AFP level as well as inflammation-related markers into consideration. Therefore, our nomograms could be regarded as a modified system by incorporating the above independent risk factors and showed significantly better prognostic performance (p < 0.001).
It remains controversy whether patients within intermediate (BCLC B) or advanced (BCLC C) stage should receive curative surgery. Several studies have demonstrated that some HCC patients in either of these two stages can benefit more from surgical resection than from the BCLC criteria recommended therapies [30]. Since many Chinese HCC patients beyond the BCLC criteria still received surgical resection, we took patients in BCLC stage B and C into analysis to extend the applied range of our nomograms. Although we included nearly a third of patients within BCLC stage C, we did an additional analysis to show that both models performed well for these patients, with a C-index of 0.743 (95% CI, 0.671 to 0.816) for OS and 0.652 (95% CI, 0.599 to 0.705) for RFS in the training cohort.
Strengths of the study were not only on the integration of inflammatory markers and specialized population, but also on its personalized predictive value of survival at early time. All the variables composited in our models are common and accurate, given that nomogram is a graphical tool generally used to integrate many independent variables according to its weight meanwhile in an easy-to-operate way. As shown in our results, the nomograms possessed great discriminatory ability which can separately stratify patients with different risks. With the nomograms, clinicians can choose to perform personalized additional interventions and shorten the interval of postoperative follow-ups if patients are evaluated to have a higher risk of recurrence and poorer survival.
Moreover, most previous studies were conducted in a single medical center. In our study, we enlarged our study population by recruiting patients from another hospital and further validated our models in this group of people. It is notable that the baseline characteristics between the training cohort and external cohort had disparity, and patients from FAHSYSU showed worsen tumor features. The possible reason is the difference in making treatment choice in these two centers. SYSUCC tended to send patients in intermediate or advanced stage to receive transcatheter arterial chemoembolization or palliative treatments, while general hospitals like FAHSYSU frequently performed surgery. Despite of the differences in baseline characteristics, our models also exhibited good prognostic value in the external cohort, with a C-index of 0.707 for RFS and 0.708 for OS, which implies that the nomograms are stable and can be adopted in different populations with high generalizability.
There are limitations in this study. First, our nomograms established using the data from HBsAg-positive HCC patients because China is an HBV prevalent region. Thus, it may restrict the application of the two nomograms in HCC patients with other aetiological backgrounds. Another one was that some inflammation-related markers are composed by overlapped hematologic and biochemical factors. Although it might possibly bias the results to some extent, we did not take the interaction among these markers into consideration while doing the analysis. Moreover, there was lack of a prospective cohort to further confirm the predictive value of our models in prognosis.
In conclusion, our study established and validated two novel prognostic nomograms which incorporated specific preoperative inflammatory markers and clinical risk variables to estimate the RFS and OS rates in HBV-related patients who underwent curative hepatectomy in a large Chinese population. The user-friendly models can be helpful to clinicians in predicting individual prognosis and deciding nextstep therapeutic interventions.
XML Download