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Background:
Systematic Review

Predictors of Mortality in Patients with Advanced Cancer—A Systematic Review and Meta-Analysis

by
Catherine Owusuaa
1,*,
Simone A. Dijkland
2,
Daan Nieboer
2,
Agnes van der Heide
2 and
Carin C. D. van der Rijt
1
1
Department of Medical Oncology, Erasmus MC Cancer Institute, P.O. Box 2040, 3000 CA Rotterdam, The Netherlands
2
Department of Public Health, Erasmus MC, Erasmus University Medical Center, P.O. Box 2040, 3000 CA Rotterdam, The Netherlands
*
Author to whom correspondence should be addressed.
Cancers 2022, 14(2), 328; https://doi.org/10.3390/cancers14020328
Submission received: 1 December 2021 / Revised: 31 December 2021 / Accepted: 7 January 2022 / Published: 11 January 2022
(This article belongs to the Special Issue Palliative and Supportive Care in Oncology: An Update)
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Abstract

:

Simple Summary

This systematic review and meta-analysis describes the predictors of mortality in patients with advanced cancer. The results indicate that disease stage, lung cancer, ECOG performance status, age, male sex, Charlson comorbidity score, and other multicomponent prognostic models could aid physicians in timely advance care planning. However, combining these predictors in a prognostic model with adequate performance requires more research.

Abstract

To timely initiate advance care planning in patients with advanced cancer, physicians should identify patients with limited life expectancy. We aimed to identify predictors of mortality. To identify the relevant literature, we searched Embase, MEDLINE, Cochrane Central, Web of Science, and PubMed databases between January 2000–April 2020. Identified studies were assessed on risk-of-bias with a modified QUIPS tool. The main outcomes were predictors and prediction models of mortality within a period of 3–24 months. We included predictors that were studied in ≥2 cancer types in a meta-analysis using a fixed or random-effects model and summarized the discriminative ability of models. We included 68 studies (ranging from 42 to 66,112 patients), of which 24 were low risk-of-bias, and 39 were included in the meta-analysis. Using a fixed-effects model, the predictors of mortality were: the surprise question, performance status, cognitive impairment, (sub)cutaneous metastases, body mass index, comorbidity, serum albumin, and hemoglobin. Using a random-effects model, predictors were: disease stage IV (hazard ratio [HR] 7.58; 95% confidence interval [CI] 4.00–14.36), lung cancer (HR 2.51; 95% CI 1.24–5.06), ECOG performance status 1+ (HR 2.03; 95% CI 1.44–2.86) and 2+ (HR 4.06; 95% CI 2.36–6.98), age (HR 1.20; 95% CI 1.05–1.38), male sex (HR 1.24; 95% CI 1.14–1.36), and Charlson comorbidity score 3+ (HR 1.60; 95% CI 1.11–2.32). Thirteen studies reported on prediction models consisting of different sets of predictors with mostly moderate discriminative ability. To conclude, we identified reasonably accurate non-tumor specific predictors of mortality. Those predictors could guide in developing a more accurate prediction model and in selecting patients for advance care planning.

1. Introduction

Advance care planning is important in patients with cancer because it enables physicians and patients to discuss and make plans for future health care [1]. It should be initiated timely in patients with advanced cancer, as a decline in the functional status of the patient, although anticipated, often occurs quickly [2]. Therefore, it is a prerequisite for the responsible physician to have insight into the limited life expectancy of their patients.
It is often suggested that patients who are likely to have a maximum life expectancy of 12 months are candidates for advance care planning. Therefore, a period of 12 months before death may be typical for patients with palliative care needs and has been included as such in quality standards worldwide [3,4]. The identification of such patients can be based on the surprise question, ‘Would you be surprised if this patient died within the next 12 months?’ [5]. Although the surprise question was initially developed to encourage physicians to refer their patients for an advance care planning program, it has also been studied as a prediction model for 12-month mortality [6]. However, it has an accuracy ranging from poor to reasonable, with a pooled accuracy level of 78.6% (95% confidence interval 69.7–86.3) for patients with cancer [7]. Other prediction models such as the Palliative Prognostic Index, the Palliative Prognostic Score, and the Palliative Performance Scale focus on a life expectancy of only weeks or a few months, which is probably too short for adequate advance care planning procedures [8].
Better insight into whether patients are likely to die within a year might aid physicians in the timely initiation of advance care planning in all patients with advanced cancer who qualify for and would benefit from it. We aimed to provide an overview of predictors and prediction models for mortality within a period of 3–24 months for patients with advanced cancer. By examining all cancer types, we intended to identify general predictors that can be applied by various caregivers.

2. Materials and Methods

2.1. Search Strategy and Selection Criteria

The search strategy, which included the terms “advanced cancer”, “mortality”, “death”, “predictor”, and “prediction model”, was developed by one researcher (CO) and an information specialist at the Erasmus MC Medical Library. They performed the search in April 2020 in the following online databases: Embase, MEDLINE, Cochrane Central, Web of Science, and PubMed (Table S1). An online study protocol for this systematic review and meta-analysis (including a search for chronic pulmonary diseases) was published at PROSPERO with registration number CRD42016038494; link: https://www.crd.york.ac.uk/PROSPERO/display_record.php?RecordID=38494 (accessed on 6 January 2022).
Studies included in this systematic review and meta-analysis had a population with (predominantly) locally advanced or metastatic cancer; studied mortality within a period of 3–24 months or found a survival between 3–24 months; reported on risk estimates (hazard ratio, odds ratio or relative risk) with their corresponding standard errors or reported on the performance of a prediction model (discriminative ability: area under the receiver operating characteristic curve [AUC], c-statistic, sensitivity, or specificity); and were published in English and from the year 2000 onwards. Both cohort studies and randomized controlled trials were assessed. We excluded systematic reviews and studies that examined mortality or survival outside the period of 3–24 months; only included patients who were treated with curative intent; had a combined outcome (e.g., mortality or hospitalization); or did not report standard errors.
The titles of papers that resulted from the search were downloaded into a reference management software program (EndNote, version X9) and screened by C.O. [9]. Afterwards, C.O. and S.A.D. independently reviewed abstracts and full-text articles to determine the studies’ inclusion. If they disagreed, the full article was reassessed, and if necessary, two other researchers (A.v.d.H. and C.C.D.v.d.R.) were involved. When duplicate study data were found in different papers, only the most recent publication was included. We requested full articles that were unavailable to us from the first author through email. We also performed a grey literature search using the bibliographies from included studies and from systematic reviews for additional relevant studies.

2.2. Data Extraction

C.O. and S.A.D. independently extracted the following data from each included study: first author, publication year, study design, study population (number of patients, age, sex, and cancer type), follow-up period, mortality rate, overall survival, risk estimates and standard errors, and the predictors and discriminative ability of a prediction model. Means were derived with standard deviations and medians with (interquartile) range. When studies reported on different follow-up periods, we only extracted the data of the longest follow-up period within the inclusion criteria. All extracted data were entered in a specifically designed Microsoft Access database.
C.O. and S.A.D. also independently extracted data to assess the risk-of-bias of individual studies using the Quality in Prognosis Studies with adapted items from the Critical Appraisal and Data Extraction for Systematic Reviews of Prediction Modelling Studies checklist [10,11]. A total of 23 items were divided over the following six domains: study participation, study attrition, predictor measurement, outcome measurement, statistical analysis and confounding, and model performance (Table S2). All items were given 2 points if bias was not present, 1 point if bias was possibly present, and 0 points if bias was obviously present. The overall risk-of-bias (low [≥80% of total points], moderate [≥60–79% of total points], or high [<60% of total points]) of each study was generated from the points given to the items per domain. Disagreements in scoring were resolved by discussion between the researchers. This study was conducted according to the Preferred Reporting Items for Systematic and Meta-analyses (PRISMA) guideline [12].

2.3. Data Analysis

The main outcomes were predictors and prediction models for mortality within a period of 3–24 months in patients with advanced cancer. The risk estimates and standard errors of predictors that were retrieved from multivariable analyses in published studies were included in the meta-analysis, provided that they were studied in ≥2 (various) cancer types [13]. We calculated the pooled overall risk estimate and standard error with a fixed-effects model for predictors that were pooled from two studies and with a random-effects model for predictors pooled from three or more studies. The fixed-effects model was preferred over the random-effects model if two studies were available, as estimates of heterogeneity become unreliable in a meta-analysis with a few studies. When applying a random-effects model, we calculated the between-study heterogeneity with the I2–statistic [14]. A heterogeneity of 0–30% was interpreted as insignificant, 40–60% as moderate, and >60% as substantial. We also performed a meta-analysis with only low risk-of-bias studies applying a fixed or random-effects model where appropriate. For performance status, we mapped different cut-offs of the Karnofsky performance scale with the Eastern Cooperative Oncology Group (ECOG) performance status [15]. All meta-analyses were conducted with the Review Manager 5.3 software (Cochrane Collaboration’s Information Management System).
For the prediction models that were studied in ≥2 (various) cancer types, we summarized the predictors and model performances. The discriminative ability measured with the AUC or c-statistic ranges from 0.5 to 1, and the closer the AUC or c-statistic is to 1, the better a model can discriminate patients who are likely to die from those who are not [16,17]. Furthermore, we identified publication bias using funnel plots [18].

3. Results

The literature search identified 6436 unique studies, of which 6265 were excluded based on their title and abstract (Figure 1). A total of 171 studies were screened for full text. Eventually, a total of 68 studies were systematically interpreted and summarized in the qualitative synthesis, whereupon 39 studies were included in the meta-analysis.
Of the included studies, 63 were cohort studies, and five were analyses from randomized controlled trials. The number of patients ranged from 42 to 66,112 among all studies and from 42 to 13,190 among studies included in the meta-analysis (Table 1). Mean and median reported ages in all studies ranged from 54.0 and 79.4 years. Thirty-three studies had a study population with ≥2 cancer types, whilst the remaining studies included patients with one type of cancer. Mortality rates within the included studies ranged from 8.3 to 94.6%. Twenty-four studies were assessed as low risk-of-bias studies, 38 as moderate risk-of-bias, and six as high risk-of-bias (Table 2). Of the risk-of-bias domains, study attrition, which included items regarding loss to follow-up and handling of missing data, was often scored as high risk-of-bias.
In the fixed-effects model, all identified predictors of mortality were significantly associated with mortality (Figure 2). Those predictors were: the surprise question (HR 7.57; 95% CI 4.41–12.99), ECOG performance status 3–4 (reference [ref]: 0; HR 3.61; 95% CI 2.58–5.05), presence of (sub)cutaneous metastases (HR 2.10; 95% CI 1.51–2.93), and the Charlson co-morbidity index score 1–2 (HR 1.28; 95% CI 1.20–1.37). Body mass index, cognitive impairment (mini-mental state examination score), serum albumin, and hemoglobin were also significant predictors of mortality.
In the random-effects model, we included 14 predictors of mortality, of which 11 were significant (Figure 3 and Figure S1). Due to the low number of studies reporting on categorical variables, we performed a separate meta-analysis for each of the sub-categories. Significant predictors were: disease stage III (pooled from three studies; HR 2.89; 95% CI 1.42–5.90); disease stage IV (pooled from three studies; HR 7.58; 95% CI 4.00–14.36); lung cancer (pooled from four studies; HR 2.51; 95% CI 1.24–5.06). Age per 10-year increase, male sex, and a Charlson comorbidity index score of 3+ were also significant predictors, as were the Karnofsky performance status, ECOG performance status 1+ (ref: 0–1), 1–2 (ref: 0), 2 (ref: 0), and 2+ (ref: 0). Non-significant predictors were ECOG performance status 1 (ref: 0), ECOG performance status (ref: 0–1), and the presence of liver metastases. There was substantial between-study heterogeneity, i.e., I2 > 60%, for the age, ECOG performance status, comorbidity, lung cancer, and liver metastasis. Furthermore, no evidence of major publication bias was identified for each predictor (Figure S2).
In a separate analysis, we only included the predictors found in low risk-of-bias studies, namely age, male sex, and ECOG performance status 1+, of which only age and male sex were significantly associated with mortality (Table S3). Variables that were excluded for the meta-analyses due to different cut-offs or definitions, or were studied in only one cancer type, are presented in Table S4.
Thirteen studies reported on and analyzed the discriminative ability of 15 different prediction models, which consisted of one variable or combined different clinical variables such as cancer type, performance status, or metastases (Table 3). Most models had a moderate discriminative ability with a c-statistic or AUC ranging from 0.6–0.8, and others, such as the (Oncological-) multidimensional prognostic index, had a good discriminative ability of >0.8. The prediction models contained different sets of variables and were examined in just one study, except the surprise question, which was examined in two studies. The external validation of only two models was described.

4. Discussion

We aimed to identify significant predictors of mortality within a period 3–24 months for patients with advanced cancer in published literature. Overall, the predictors we found can be categorized into three main groups: the surprise question; clinical variables (age, male sex, disease stage, performance status, comorbidity, cognitive impairment, (sub)cutaneous metastases, and lung cancer); and laboratory variables (serum albumin and hemoglobin). Almost all predictors were non-tumor specific and may improve the identification of cancer patients at risk of death in the set time period. Better identification might enable conversations on advance care planning. However, the usefulness of some predictors in the clinical setting may be questionable. It might seem obvious that an advanced disease stage (III or IV) compared to a localized stage (I) is associated with mortality. Considering hemoglobin, it is unknown whether chemotherapy-induced or tumor-induced anemia were specifically considered, although this may be relevant. Furthermore, the identified predictors might not be exclusively associated with mortality within 3–24 months. For example, the performance status of a patient is, on the one hand, included in indexes to predict the terminal phase, such as in the Palliative Prognostic Score, the Palliative Prognostic Index, and the Chuang Prognostic Score [87]. On the other hand, the performance status is also included in tumor-specific indexes to predict mortality within a longer time frame exceeding 24 months [88,89,90].
The advantage of non-tumor specific predictors is that they apply to patients with various types of cancer. Furthermore, those predictors could be used by both medical specialists and other physicians, such as general practitioners. In theory, studies that were conducted in heterogeneous groups of patients, i.e., patients with various types of cancer, comorbidity and other characteristics, were most useful for our study. However, approximately half of the studies included patients with a specific type of cancer or a specific complication, as for example, bone metastases. To find non-tumor specific predictors in the meta-analysis, we only included predictors that were examined in heterogeneous study populations or in at least two groups of patients with different types of cancer. As a result, we observed substantial heterogeneity across studies in the meta-analysis for the predictors: age, the different variants of ECOG performance status, Charlson comorbidity index, lung cancer, and liver metastasis. However, the observed heterogeneity may also have been caused by different follow-up periods in the separate studies, different mortality rates, and differences between studies regarding the percentage of patients with locally advanced vs metastatic disease. Therefore, the substantial heterogeneity we found for the mentioned predictors can be expected. For example, the presence of liver metastasis in a patient with stomach cancer probably has a worse prognosis than in a patient with breast cancer. In addition, a patient with a poor performance status might seem to have a worse prognosis when examining a period of 24 months compared to a period of six months. Nevertheless, although heterogeneity was found between studies, we found various generic predictors of mortality. To optimize the prediction of mortality in a heterogeneous cancer population, multiple predictors must be considered together. We recommend the examination of several predictors in a prospective study in a heterogeneous cancer population.
Our study demonstrates the clinical importance of the surprise question, which was one of the most significant predictors in the meta-analysis. However, this finding should be interpreted with some caution because the surprise question was examined in only two studies. Furthermore, it is important to bear in mind that the surprise question has an aspect of subjectivity because it relates to the physician’s opinion [91]. Therefore, the generalizability of the surprise question might be questioned. Despite this, the surprise question is commonly used in the identification of patients with palliative care needs and included in palliative care needs assessment tools, such as the RADboud indicators for Palliative Care needs (RADPAC), Supportive and Palliative Care Indicators Tool (SPICT), and Prognostic Indicator Guide (PIG) [92]. Despite the fact that the surprise question is widely believed to be useful, there is abundant room for discussion concerning whether it should be used as a predictor of mortality, possibly combined with other variables, or only included in the assessment of palliative care needs [93,94].
Remarkably, apart from the surprise question, all other prediction models consisted of different variables or sets of variables. Their discriminative ability was mostly moderate, and some were good. However, a note of caution is due in the applicability of almost all the models since their calibration, which shows observed and predicted risk of mortality, was not studied. Another source of caution is the lack of external validation of the models. Despite the possible limitations of the models, two models with a good discriminative ability might be interesting for further study: the Patient-generated Subjective Global Assessment, which was externally validated; and the Oncological-multidimensional prognostic index, which had a good calibration. Nonetheless, there is a definite need for a general, high-quality prediction model for the accurate prediction of mortality in patients with advanced cancer.
This study had some limitations. Firstly, because we performed a meta-analysis, some predictors with slight differences in measuring units or cut-offs could not be pooled. An example of such a predictor was weight loss, which was studied at various cut-offs of kilograms. Therefore, the number of pooled studies for each predictor was small, e.g., the inclusion of two studies, which might limit the strength of a meta-analysis. Secondly, studies with moderate or high risk-of-bias scored poorly on the study attrition of our modified QUIPS tool. Lastly, the inclusion of published studies, exclusively from 2000 onward, could have led to the exclusion of some predictors of mortality.

5. Conclusions

The surprise question and general clinical (age, male sex, disease stage, performance status, comorbidity, cognitive impairment, (sub)cutaneous metastases, and lung cancer) and laboratory variables (serum albumin and hemoglobin) are non-tumor specific predictors of mortality within 3–24 months in patients with advanced cancer. Physicians could apply those predictors of mortality within 3–24 months in the timely initiation of advance care planning. Due to the lack of high-quality prediction models, the identified predictors can provide guidance in selecting candidate predictors for future prospective studies, which will explore the development of a general prediction model for mortality. Furthermore, future research should also examine the association of using such a prediction model with the timely initiation of advance care planning.

Supplementary Materials

The following are available online at https://www.mdpi.com/article/10.3390/cancers14020328/s1, Table S1: Search strategy for the online databases, Table S2: Domains and items for risk-of-bias assessment, Table S3: Hazard ratios for mortality based on studies with low risk-of-bias, Table S4: Variables not included in the meta-analysis, Figure S1: Forest plots per individual predictor using random-effects model, Figure S2: Funnel plots.

Author Contributions

C.O., S.A.D., A.v.d.H. and C.C.D.v.d.R. developed the concept and study design. C.O. and S.A.D. acquired data. C.O., S.A.D. and D.N. evaluated and analyzed the data. C.O. drafted the initial manuscript. The corresponding author had full access to all the data in the study and had final responsibility for the decision to submit for publication. All authors have read and agreed to the published version of the manuscript.

Funding

This research was funded by the Netherlands Organization for Health Research and Development (ZonMw) [grant number 844001209].

Acknowledgments

We thank researcher Hester F. Lingsma for her assistance in designing the study. We also thank Gerdien B. de Jonge, Biomedical Information Specialist at the Erasmus MC Medical Library, for her assistance with the systematic search.

Conflicts of Interest

The authors declare no conflict of interest. The funders had no role in the design of the study; in the collection, analyses, or interpretation of data; in the writing of the manuscript, or in the decision to publish the results. The corresponding author had full access to all the data in the study and had final responsibility for the decision to submit for publication.

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Cancers 14 00328 g001 550
Figure 1. Study selection.
Figure 1. Study selection.
Cancers 14 00328 g001
Cancers 14 00328 g002 550
Figure 2. Forest plot of pooled hazard ratios for mortality with a fixed-effects model. CI: confidence interval; HR: hazard ratio; ECOG: Eastern Cooperative Oncology Group.
Figure 2. Forest plot of pooled hazard ratios for mortality with a fixed-effects model. CI: confidence interval; HR: hazard ratio; ECOG: Eastern Cooperative Oncology Group.
Cancers 14 00328 g002
Cancers 14 00328 g003 550
Figure 3. Forest plot of pooled hazard ratios for mortality with a random-effects model. CI: confidence interval; HR: hazard ratio; ECOG: Eastern Cooperative Oncology Group.
Figure 3. Forest plot of pooled hazard ratios for mortality with a random-effects model. CI: confidence interval; HR: hazard ratio; ECOG: Eastern Cooperative Oncology Group.
Cancers 14 00328 g003
Table
Table 1. Study characteristics of all 68 studies reporting predictors of mortality or prediction models.
Table 1. Study characteristics of all 68 studies reporting predictors of mortality or prediction models.
Study
(First Author,
Publication Year)		Study DesignN PatientsStudy PopulationAge (Years)Men (%)Follow-Up (Months)Mortality Rate (%)Survival (Months)Inclusion in
Meta-Analysis		Inclusion of
a Model
1Bartels, 2007 [19]Cohort219Spinal epidural metastases;
various cancer types		62.7 ± 12.558.410n/a3.0
(0.0–74.4)		++
2Braun, 2011 [20]Cohort1194Stage I–IV NSCLC58.5
(21.6–86.4)		50.3n/a65.28.8
(8.0–9.5)		+-
3Brunello, 2016 [21]Cohort658Stage I–IV; various cancer types77.2 ± 5.134.21217.4n/a++
4Cesari, 2013 [22]Cohort200Stage I–IV ovarian or uterine cancer73.5 ± 6.20.01211.5n/a++
5Chen, 2019 [23]Cohort121Gastric adenocarcinoma;
stage I–IV		64.0 ± 14.960.31232.2n/a--
6Chow, 2008 [24]Cohort395Metastatic disease, referred for palliative radiotherapy; various cancer types68.0
(31.0–93.0)		50.012n/a4.4
(3.9–6.4)		++
7Collette, 2004 [25]RCT391Metastatic hormone-refractory prostate cancer70.8
(34.3–89.3)		100.01242.710.4
(9.2–11.5)		++
8Collins, 2014 [26]Cohort1160Malignant glioman/a58.4423.0n/a--
9Contreras-Bolívar, 2019 [27]Cohort282Various cancer types60.4 ± 12.655.7647.9n/a--
10Deans, 2007 [28]Cohort220Stage I–IV gastric or esophageal cancer71.0
(62.0–78.0)		65.92461.813.0 (n/a)++
11Dharma-Wardene, 2004 [29]Cohort42Stage IIIA/B or IV NSCLC or SCLC59.4
(39.0–78.0)		45.22416.79.9 (n/a)+-
12Efficace, 2006 [30]RCT391Stage IIIB–IV NSCLC57.0
(28.1–75.9)		65.2n/a77.2(6.7–8.9)+-
13Ferrigno, 2001 [31]Cohort343Stage 0–IV bronchogenic
carcinoma		68.0
(39.0–86.0)		88.68.5
(3.6–17.4)		79.0n/a--
14Fielding, 2007 [32]Cohort358Lung (analysis, stage I–IV)n/a, subgroups of
different ages available		75.73.2
(2.0–7.0)		78.5n/a++
15Filippini, 2008 [33]Cohort676Newly-diagnosed glioblastoma58.0
(16.0–81.0)		61.82484.013.6
(12.9–14.3)		+-
16Gagnon, 2013 [34]Cohort258Inoperable stage III–IV NSCLCn/a50.012n/a(2.5–18.2)-+
17Geraci, 2006 [35]Cohort372Acutely symptomatic cancer patients; various cancer types56.0
(15.0–96.0)		49.0630.0n/a--
18Giantin, 2013 [36]Cohort160Inoperable, locally advanced or metastatic cancer; various
cancer types		79.4 ± 5.745.51246.9n/a++
19Griguolo, 2018 [37]Cohort668Invasive breast cancer,
brain metastases		56.0
(24.0–85.0)		0.1n/a94.68.1
(6.9–9.4)		+-
20Gripp, 2007 [38]Cohort216Patients examined for palliative radiation; various cancer types64.0
(21.0–96.0)		51.0651.4n/a--
21Gupta, 2004 [39]Cohort58Stage IV pancreatic cancer56.2 ± 10.760.3n/a72.4(4.9–10.2)--
22Gupta, 2009 [40]Cohort165Stage IIIB or IV NSCLC56.0
(30.0–78.0)		56.4n/a67.3(6.8–16.8)--
23Hoang, 2005 [41]RCT1436Stage IIIB or IV NSCLCn/a 63.02489.08.2 (n/a)++
24Hong, 2016 [42]Cohort183Advanced HCCMean 55.886.3674.9n/a-+
25Hosono, 2005 [43]Cohort165Spinal metastases; various
cancer types		n/an/a23.4
(0.3–140.0)		n/an/a --
26Hui, 2014 [44]Cohort222Advanced cancer, seen by
palliative care mobile team; various cancer types		55.0
(22.0–79.0)		41.03.9
(0.9–7.9)		64.03.6
(2.3–4.2)		+-
27Hui, 2016 [45]Cohort216Advanced cancer, seen by the palliative care mobile team; various cancer types54.9
(22.0–79.0)		42.07.9
(6.9–8.6)		63.03.6
(2.3–4.4)		-+
28Iversen, 2009 [46]Cohort13,190Stage I–IV colorectal cancern/a47.012n/an/a+-
29Jang, 2014 [47]Cohort1655Advanced cancer; various
cancer types		65.0
(21.0–97.0)		49.0n/a91.04.4
(4.0–4.7)		-+
30Jonna, 2016 [48]Cohort803Stage I–IV; various cancer types72.5 (n/a)51.81277.34.9 (n/a)++
31Katagiri, 2005 [49]Cohort350Bone metastases; various cancer types59.0
(14.0–88.0)		56.92467.0n/a+-
32Kilgour, 2013 [50]Cohort203Locally, advanced and
metastatic cancer; various
cancer types		64.3 ± 12.857.1n/a76.67.3
(5.3–9.3)		--
33Kim, 2009 [51]Cohort325UICC stage I–IV
newly-diagnosed HCC		58.8 ± 9.580.92446.414.7
(2.0–88.0)		-+
34Kinoshita,
2012 [52]		Cohort133Stage I–IV HCC71.0
(43.0–87.0)		70.722.0
(1.0–69.0)		13.0–91.4n/a+-
35Langendijk,
2000 [53]		Cohort198Stage I–IIIB NSCLCn/a85.0n/an/a(2.8–13.8)--
36Liljehult, 2017 [54]Cohort109Glioblastoma65.0 ± 9.956.91255.0n/a--
37Limquiaco,
2009 [55]		Cohort471Stage I–IV HCC58.8 ± 12.285.1645.010.1 ± 10.3-+
38Lund, 2009 [56]Cohort 2315Renal cancerMen: 68.0 (15.0–96.0); women: 70.0 (18.0–97.0) 58.71236.9n/a+-
39Maione, 2005 [57]RCT566Stage IIIB–IV NSCLC74.0
(70.0–84.0)		82.012686.9
(6.4–7.8)		+-
40Marrero, 2005 [58]Cohort244Stage I–IV HCC57.0 ± 10.073.01242.016.4
(12.9–19.8)		+-
41Martin, 2010 [59]Cohort1164Metastatic cancer; various
cancer types		66.8 ± 13.049.03.1
(0.0–38.6)		86.4n/a++
42Moroni, 2014 [60]Cohort231Advanced cancer; various
cancer types		70.2 ± 0.950.61245.0n/a++
43Moss, 2010 [61]Cohort826Stage I–IV breast, lung, and
colon cancer		60.0 ± 13.014.8128.3n/a++
44Motzer, 2004 [62]Cohort251Stage IV renal cell carcinoma57.0
(23.0–77.0)		67.02476.010.2
(8.0–12.0)		+-
45Norman, 2010 [63]Cohort399Stage I–IV; various cancer types63.0 ± 11.852.1625.1n/a+-
46Orskov, 2016 [64]Cohort2654Stage I–IV ovary cancern/a0.01216.0n/a--
47Park, 2016 [65]Cohort403Metastatic or recurrent
pancreatic ductal
adenocarcinoma		66.0
(29.0–96.0)		49.17.9
(0.1–70.5)		n/a8.2
(7.3–9.1)		++
48Penel, 2008 [66]Cohort119Bone metastases; various cancer types57.0
(29.0–84.0)		64.7334.03.9
(0.0–94.5)		++
49Penel, 2008 [67]Cohort148Patients screened for phase 1 trial; various cancer types54.0
(23.0–79.0)		n/a373.05.7
(0.0–79.6)		+-
50Pinato, 2015 [68]Cohort97Intermediate-advanced HCC64.0
(22.0–82.0)		80.0n/a71.05.7
(1.0–88.0)		-+
51Pointillart, 2011 [69]Cohort142Vertebral metastases; various cancer types61.8
(28.0–89.0)		57.01250.75.0 (n/a)+-
52Roychowdhury, 2003 [70]Cohort364Locally advanced or metastatic urothelial transitional-cell
carcinoma		63.5 (n/a)79.1n/an/a14.2
(13.1–16.8)		--
53Rydzek, 2015 [71]Cohort326Breast cancer, SCLC or NSCLC; patients with established
cardiovascular disease		67.8 ± 10.054.012n/a(4.8–96.0)+-
54Schoenfeld,
2020 [72]		Cohort1216Various cancer types, spinal metastases58.0 ± 9.750.01247.08.4
(3.1–21.1)		--
55Scott, 2002 [73]Cohort106Stage III–IV NSCLC69.0
(43.0–87.0)		58.5n/an/a5.2
(0.3–38.5)		+-
56Seow, 2013 [74]Cohort11,342Various cancer types, patients with PPS assessment64.0 ± n/a45.6625n/a+-
57Shen, 2007 [75]Cohort49HCC, patients underwent TACE57.0 ± 1.081.6n/a49.012.0
(1.0–72.0)		--
58Soubeyran,
2012 [76]		Cohort348Various cancer types; 65%
advanced stage		77.5
(70.0–99.4)		59.5616.1n/a+-
59Sutradhar,
2014 [77]		Cohort66,112Various cancer typesn/a43.819.3 (n/a)26.3n/a-+
60Suzuki, 2020 [78]Cohort185Advanced urothelial cancer70.0
(64.0–76.0)		68.01271.914.9 (n/a)--
61Tsai, 2014 [79]Cohort522Advanced cancer; various
cancer types		60.6 ± 13.261.7691.8n/a--
62Tripodoro,
2019 [80]		Cohort317Various cancer types, stage III or IV77.0
(21.0–99.0)		33.42474.84.0 (n/a)--
63Ueno, 2000 [81]Cohort103Metastatic pancreatic cancer62.0
(42.0–75.0)		68.01294.4 3.2 (n/a)+-
64van der Linden, 2005 [82]RCT342Spinal metastases; various
cancer types		66.0
(34.0–90.0)		53.02475.011.0
(10.0–12.0)		--
65Vigano, 2000 [83]Cohort227Inoperable, recurrent,
progressive or metastatic
cancer; various cancer types		62.0
(29.0–92.0)		36.12091.65.8 (n/a)+-
66Villa, 2011 [84]Cohort285Newly-diagnosed brain
metastases; various cancer types		62.0
(20.0–90.0)		n/a1282.4n/a++
67Wei, 2019 [85]Cohort71Pneumonic-type adenocarcinoma, 90% with stage IIIB or IV62.0
(25.0–91.0)		45.1684.57.5
(1.0–42.0)		+-
68Yamashita,
2011 [86]		Cohort85Spinal metastases; various
cancer types		60.3 ± 11.651.81251.8n/a--
H: high risk-of-bias; HCC: hepatocellular carcinoma; L: low risk-of-bias; M: moderate risk-of-bias; N: number of patients; n/a: not available; NSCLC: non-small cell lung cancer; PPS: Palliative Performance Scale; RCT: randomized controlled trial; SCLC: small cell lung cancer; TACE: trans arterial chemoembolization; UICC: Union Internationale Contre le Cancer.
Table
Table 2. Summary of risk-of-bias assessment.
Table 2. Summary of risk-of-bias assessment.
StudyStudy ParticipationStudy AttritionPredictorsOutcomeStatistical Analysis and CofoundingPerformance of Prediction ToolOverall Bias
Bartels, 2007 [19]LHMLLMM
Braun, 2011 [20]LHLLLn/aL
Brunello, 2016 [21]LHLLMMM
Cesari, 2013 [22]LHLLMMM
Chen, 2019 [23]LMLLHn/aM
Chow, 2008 [24]LHLMMLM
Collette, 2004 [25]MHLLLMM
Collins, 2014 [26]LMLLLn/aL
Contreras-Bolívar,
2019 [27]		LMLLLn/aL
Deans, 2007 [28]LMLLLML
Dharma-Wardene,
2004 [29]		LHLLMn/aM
Efficace, 2006 [30]LHMLLn/aM
Ferrigno, 2001 [31]LHLLLn/aL
Fielding, 2007 [32]LHLLLMM
Filippini, 2008 [33]LMMLLn/aL
Gagnon, 2013 [34]LHLMLLM
Geraci, 2006 [35]LHLLLn/aL
Giantin, 2013 [36]LHLLLMM
Griguolo, 2018 [37]LHLLLn/aL
Gripp, 2007 [38]LHLLLn/aL
Gupta, 2004 [39]LHLLLn/aL
Gupta, 2009 [40]LMLLMn/aL
Hoang, 2005 [41]LHMLLHH
Hong, 2016 [42]LHLLMMM
Hosono, 2005 [43]MHMLMn/aH
Hui, 2014 [44]LHLLLn/aL
Hui, 2016 [45]LHLLHMH
Iversen, 2009 [46]LHLLMn/aM
Jang, 2014 [47]LHLLHMH
Jonna, 2016 [48]LHMLLMM
Katagiri, 2005 [49]LHMLMn/aM
Kilgour, 2013 [50]LLLLMn/aL
Kim, 2009 [51]LHMLMMH
Kinoshita, 2012 [52]LHLLMn/aM
Langendijk, 2000 [53]LHLMMn/aM
Liljehult, 2017 [54]MHLLMn/aM
Limquiaco, 2009 [55]LHLLLMM
Lund, 2009 [56]LMLLHn/aM
Maione, 2005 [57]LHLLMn/aM
Marrero, 2005 [58]LMMLMn/aM
Martin, 2010 [59]LHLLLLL
Moroni, 2014 [60]LHLLLMM
Moss, 2010 [61]LHLLLMM
Motzer, 2004 [62]LHLLLn/aL
Norman, 2010 [63]LHLLMn/aM
Orskov, 2016 [64]LMLLMn/aL
Park, 2016 [65]LHLMLMM
Penel, 2008 [66]LHMLMMH
Penel, 2008 [67]LHLLMn/aM
Pinato, 2015 [68]LHMLLLM
Pointillart, 2011 [69]LHLLMn/aM
Roychowdhury,
2003 [70]		LHLMMn/aM
Rydzek, 2015 [71]LHLMMn/aM
Schoenfeld, 2020 [72]LHLLLn/aL
Scott, 2002 [73]LLLLLn/aL
Seow, 2013 [74]LHLLMn/aM
Shen, 2007 [75]LHLLLn/aL
Soubeyran, 2012 [76]LHLLHn/aM
Sutradhar, 2014 [77]LHMLLMM
Suzuki, 2020 [78]LHMLLn/aM
Tripodoro, 2019 [80]LHLLMn/aM
Tsai, 2014 [79]LMLLLn/aL
Ueno, 2000 [81]LHLLLn/aL
van der Linden,
2005 [82]		LMLLMn/aL
Vigano, 2000 [83]LMLLLn/aL
Villa, 2011 [84]LMMLLMM
Wei, 2019 [85]LMMMMn/aM
Yamashita, 2011 [86]LHLLLn/aL
H: high risk-of-bias; L: low risk-of-bias; M: moderate risk-of-bias; n/a: not applicable.
Table
Table 3. Summary of the prediction models.
Table 3. Summary of the prediction models.
Variables
StudyFUNName ModelCancer TypePerformance StatusCancer TreatmentSexLaboratory ResultsMetastasesDisease StageAgeCognitive ImpairmentDietary IntakeWeight ChangeBody Mass IndexSurprise QuestionComorbidity(Re)hospitalizationOtherDiscriminative AbilityCalibrationExternal Validation
Bartels, 2007 [19]10219n/a**** * c-statistic 0.72
(95% CI 0.68–0.77)		n/an/a
Brunello, 2016 [21]12658Onco-MPI**
*		 * *** * *
*
*		c-statistic 0.869
(95% CI 0.841–0.897)		Goodn/a
Cesari [22]12200IADL *AUC 0.676
(95% CI 0.532–0.821)		n/an/a
SPPB *AUC 0.638
(95% CI 0.483–0.792)		n/an/a
UGS *AUC 0.686
(95% CI 0.560–0.812)		n/an/a
Chow, 2008 [24]12395n/a** * c-statistic 0.66n/aN = 467
c-statistic 0.63
Deans, 2007 [28] 24220u/a * * * * AUC 0.85n/an/a
Giantin, 2013 [36]12160MPI* * * *
*
*		AUC 0.874
(95% CI 0.819–0.928)		n/an/a
Jang, 2014 [47]n/a1655KPS * c-statistic 0.63n/an/a
PPS * c-statistic 0.63n/an/a
ECOG * c-statistic 0.64n/an/a
Jonna, 2016 [48]12803n/a* ** * * *
*		*c-statistic 0.66
(95% CI 0.58–0.72)		n/an/a
Martin, 2010 [59]3.11164PG-SGA** ** *c-statistics 0.88
(95% CI 0.83–0.91)		n/aN = 603
c-statistic 0.87
(95% CI 0.80–0.92)
Moroni, 2014 [60]12231Surprise question * Se 69.3 (95% CI 60.5–77.2)/
Sp 83.6 (95% CI 75.1–90.2)/
PPV = 83.8 (95% CI 75.3–90.3)/
NPV = 69.0 (95% CI 60.2–77.0)		n/an/a
Moss, 2010 [61]12826Surprise question * Se 75/Sp 90/PPV 41/NPV 97n/an/a
Penel, 2008 [66]3119 * *
*
*		*
*
*		 Se 0.21–0.89/Sp 0.33–0.96/
Positive LR 0.40–0.78/
Negative LR 0.72–0.85/		n/an/a
Sutradhar, 2014 [77]19.366,112n/a* * * * *c-statistic 0.764–0.872
(95% CI 0.758–0.878)		n/an/a
ECOG: Eastern Cooperative Oncology Group; FU: follow-up; KPS: IADL: instrumental activities of daily living; Karnofsky Performance Status; LR: likelihood ratio; MPI: multidimensional prognostic index; n/a: not available; NPV: negative predictive value; Onco-MPI: Oncological-multidimensional prognostic index; PG-SGA: Patient-generated Subjective Global Assessment; PPS: Palliative Performance Scale; PPV: positive predictive value; Se: sensitivity; Sp: specificity; SPPB: Short Physical Performance Battery; UGS: usual gait speed. Legend: an asterisk represents the presence of the variable, whereby two or more asterisks per variable represent different subcategories.
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Owusuaa, C.; Dijkland, S.A.; Nieboer, D.; van der Heide, A.; van der Rijt, C.C.D. Predictors of Mortality in Patients with Advanced Cancer—A Systematic Review and Meta-Analysis. Cancers 2022, 14, 328. https://doi.org/10.3390/cancers14020328

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Owusuaa C, Dijkland SA, Nieboer D, van der Heide A, van der Rijt CCD. Predictors of Mortality in Patients with Advanced Cancer—A Systematic Review and Meta-Analysis. Cancers. 2022; 14(2):328. https://doi.org/10.3390/cancers14020328

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Owusuaa, Catherine, Simone A. Dijkland, Daan Nieboer, Agnes van der Heide, and Carin C. D. van der Rijt. 2022. "Predictors of Mortality in Patients with Advanced Cancer—A Systematic Review and Meta-Analysis" Cancers 14, no. 2: 328. https://doi.org/10.3390/cancers14020328

APA Style

Owusuaa, C., Dijkland, S. A., Nieboer, D., van der Heide, A., & van der Rijt, C. C. D. (2022). Predictors of Mortality in Patients with Advanced Cancer—A Systematic Review and Meta-Analysis. Cancers, 14(2), 328. https://doi.org/10.3390/cancers14020328

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