Research Article | Open Access
Coagulation Parameters and Risk of Progressive Hemorrhagic Injury after Traumatic Brain Injury: A Systematic Review and Meta-Analysis
Intracranial hemorrhage (ICH) after traumatic brain injury (TBI) commonly increases in size and coagulopathy has been implicated in such progression. Our aim is to perform a meta-analysis to assess their relationship. Cochrane library, PubMed, and EMBASE were searched for literatures. Pooled effect sizes and 95% confidential intervals (CIs) were calculated using random-effects model. We included six studies, involving 1700 participants with 540 progressive hemorrhagic injuries (PHIs). Our findings indicate that PT, D-dimer level, and INR value are positively associated with the risk of PHI. Higher level of PLT and Fg seemed to suggest a lower risk of PHI. Among these parameters, higher D-dimer level and INR value would possess more powerful strength in predicting PHI.
Traumatic brain injury (TBI) remains the leading cause of death after trauma, often leading to long term physical and neuropsychiatric deficits [1–6]. Although some damage to the brain occurs in the initial of injury, secondary brain damage due to ongoing intracranial bleeding and brain swelling is an eminent and potentially avoidable cause of morbidity and mortality. Of many potential secondary processes, progressive hemorrhagic injury (PHI) is one of the most important and devastating issues .
PHI is generally defined as the appearance of new hemorrhage lesion or evident expansion of previous hematoma [8–13], with an incidence ranging from 6% to 67% [8–26]. Traditionally, PHI is diagnosed by repeated CT scanning before irreversible deterioration occurs. Nevertheless, practices of some trauma centers turned out to be time-consuming and costly . Therefore, addressing risk factors closely associated with PHI would be of great avail. Several factors, such as male gender, low initial level of consciousness, older age, and presence of the spot sign on CT angiography and coagulopathy, have been implicated as impact factors of intracranial hemorrhage (ICH) progression [8, 27–29]. Coagulopathy, traditionally diagnosed by routine laboratory tests such as international normalized ratio (INR), activated partial thromboplastin time (APTT), and platelet count (PLT), is common in TBI and may be a potential prognostic factor.
However, data regarding the association between laboratory tests and PHI have been somewhat inconsistent. Stein and associates indicated that abnormal values of INR, APTT, and PLT were independently correlated with PHI . A study by Oertel and colleagues found that only prolonged PTT was associated with PHI , whereas Engström and coworkers reported that only low PLT count was related to PHI . In view of discrepancies among literatures, the purpose of our meta-analysis is to explore the relationship between coagulation tests and PHI to improve evidence-based management of patients with TBI.
2.1. Search Strategy
Two investigators (Danfeng Zhang and Shun Gong) independently searched Cochrane Library, PubMed, and Embase for pertinent studies examining the association between coagulation parameters and the risk of PHI after TBI. Six main coagulation parameters at admission were investigated, respectively. The search was limited to studies published between 1970 and October 2014. The language was restricted to English. The reference lists of retrieved articles were scrutinized to identify additional relevant studies.
2.2. Definition of PHI
We defined PHI as “the appearance of new lesion(s) or a conspicuous increase in the size of hemorrhagic lesion(s), which amounted to no less than a 25% or more increase versus the first post-injury CT scan” . The exact definitions of PHI and cutoff points of each coagulation parameter in included studies are given in Table 1.
|APTT: activated partial thromboplastin time; D-D: D-dimer; DTICH: delayed traumatic intracerebral/intracranial hemorrhage; Fg/FIB: fibrinogen/fibrin; INR: international normalized ratio; N/A: not available; PHI: progressive hemorrhagic injury; PIH: progressive intracerebral/intracranial hemorrhage; PLT: platelet counts; PT: prothrombin time; SD: standard deviation.|
2.3. Selection Criteria
Studies were considered eligible if they (1) were controlled observational studies; (2) included people suffering TBI; (3) investigated the relationship between abnormal coagulation tests and PHI.
2.4. Data Extraction and Quality Assessment
Three authors (Danfeng Zhang, Shun Gong, and Hai Jin) extracted the data in standardized data-collection forms, and 2 authors (Wei Zou and Ping Sheng) assessed the study quality. The Newcastle-Ottawa Scale was used to evaluate the methodological quality . Disagreements among reviewers were resolved by joint review.
2.5. Statistical Analysis
We pooled continuous and dichotomous data extracted from pertinent articles, respectively, using the random-effects model. When both data were available in one paper, they were pooled into different aspects of our meta-analysis. Mean difference and odds ratio (OR) were selected as the effect sizes. Correlation coefficient was calculated to assess the association strength for each parameter. A threshold of was used to decide whether heterogeneity was present . In other ways, values were 2 sided, with significance level of 0.05. Heterogeneity was mainly assessed by the statistic. We considered low, moderate, and high values to be 25%, 50%, and 75%, respectively . Sensitivity analyses were also performed. Stata software (version 12.0; Stata Corporation, College Station, TX) was used for the meta-analysis.
3.1. Literature Search
The results of study-selection process were shown in Figure 1. Initial search produced 5 studies from Cochrane library, 143 studies from PubMed, and 611 studies from Embase. After exclusion of duplicates and irrelevant studies, 33 potentially eligible studies were selected. After detailed evaluations, 6 studies were selected for final meta-analysis. A manual search of reference lists of these studies yielded 2 eligible studies.
3.2. Study Characteristics
A total of 6 studies were included for the meta-analysis, consisting of 4 case-control studies [9–11, 13] and 2 nested case-control studies [8, 12], totaling 1700 subjects with 540 PHIs (Table 2). Subjects in included studies were divided into two groups: PHI-positive group and PHI-negative group. Two studies were conducted in American populations [8, 13] and four in Chinese populations [9–12]. Four studies reported both dichotomous and continuous data for relevant coagulation tests [8–10, 12]. Qualities of included studies were good after assessment (Table 3). Effect sizes and strengths of association between coagulation tests and PHI were summarized in Tables 4 and 5, respectively.
|APTT: activated partial thromboplastin time; D-D: D-dimer; DTICH: delayed traumatic intracerebral/intracranial hemorrhage; Fg/FIB: fibrinogen/fibrin; INR: international normalized ratio; N/A: not available; PHI: progressive hemorrhagic injury; PIH: progressive intracerebral/intracranial hemorrhage; PLT: platelet counts; PT: prothrombin time; SD: standard deviation. |
|0 = “no,” “unable to determine,” or “not available.”|
|APTT: activated partial thromboplastin time; Fg: fibrinogen/fibrin; INR: international normalized ratio; PHI: progressive hemorrhagic injury; PLT: platelet counts; PT: prothrombin time; CI: confidence interval; MD: mean difference; OR: odds ratio. |
|APTT: activated partial thromboplastin time; Fg: fibrinogen/fibrin; INR: international normalized ratio; PHI: progressive hemorrhagic injury; PLT: platelet counts; PT: prothrombin time; .|
3.3. Coagulopathy and Risk of PHI
3.3.1. Coagulation Parameters in PHI versus Non-PHI (Continuous Data)
PLT and PHI. Four studies were included to investigate the association between decreased PLT counts and the incidence of PHI following TBI [8, 10, 12, 13]. No significant effect was detected after the meta-analysis ().
PT and PHI. Two studies were available for meta-analysis with heterogeneous outcomes [8, 10]. The overall result demonstrated no significant effect, with a mean difference of 0.25 (95% CI, −0.60–1.11; ).
D-Dimer and PHI. Two studies probed the potential effect of D-dimer [10, 12] on PHI. Significantly increased D-dimer values were found in both studies, which raised no statistically significant result after pooling together, with a mean difference of 34.48 (95% CI, −32.15–101.11; ).
Fg and PHI. We identified three studies [9, 10, 12], two of which showed decreased Fg in patients with PHI. The overall meta-analysis showed a tendency towards Fg reduction in PHI-positive patients: MD of −0.26 (95% CI, −0.39–−0.13; ), with no heterogeneity (, ).
INR and PHI. Two recent studies examining possible relationship between INR and PHI both detected a higher INR in PHI-positive patients [12, 13]. However, gathering extracted data brought out marginal statistical significance [MD: 0.50 (95% CI, −0.09–1.08; )].
3.3.2. Prevalence of PHI in Normal Coagulation versus Coagulopathy (Dichotomous Data)
PLT and PHI. Dichotomous data for PLT were retrievable from four studies [8–11]. Meta-analysis of included studies suggested statistically significant association between PLT reduction and subsequent PHI, with a pooled OR of 2.76 (95% CI, 1.62–4.70; ).
PT and PHI. Meta-analysis was possible for five studies examining PT values for both groups and reporting dichotomous data [8–12]. Overall, there was a significant increased incidence of PHI with prolonging PT value (OR, 2.69; 95% CI, 1.55–4.66; ).
PTT and PHI. Potential link between PTT and PHI was assessed in four studies [8–11]. The pooled result failed to prove such association (OR, 2.39; 95% CI 0.72–7.95; ), with a moderate degree of heterogeneity (%; ).
Fg and PHI. Three case-control studies were aggregated to unravel the possible effect of abnormal Fg on the genesis of PHI [9–11]. The summary result favored a strong efficacy of decreased Fg to bring about PHI (OR, 3.44 95% CI, 2.37–4.99; ).
INR and PHI. Meta-analysis was conducted for two studies [11, 13]. General inverse variance method was adopted because of the lack of absolute data in White 2009. Positive associations between INR and PHI were found (OR, 3.70; 95% CI, 1.11–6.29; ).
3.4. Risk Factor Estimates for PHI Associated with Coagulopathy
In order to unravel the connection intensity for each parameter, the correlation coefficient was calculated and assessed through statistical process. As the above, we analyzed both data types, respectively.
3.4.1. Analysis of Continuous Data
Meta-analysis of pertinent studies implied a strong strength for Fg reduction (; 95% CI, −0.23–−0.04; ) and abnormal INR (, 95% CI, 0.36–0.59; ) in predicting PHI. Four studies were retrieved for PLT, with an overall effect size of −0.07. Only marginal statistical significance was detected for D-dimer (; ). Overall analysis gave rise to a nonsignificant effect for PT () and PTT ().
3.4.2. Analysis of Dichotomous Data
Powerful impact strength was detected for D-dimer, with summary relative risk of 0.66 (95% CI, 0.44–0.81; ). Meta-analysis of dichotomous data confirmed moderate statistical association for INR (), PT (), PLT (), and Fg (). The pooled result failed to prove significance for PTT ().
3.5. Sensitivity Analysis
To explore whether our results were influenced by a particular study, we carried out a leave-one-out sensitivity analysis, in which one study at a time was excluded and the remaining ones were analyzed. In sensitivity analysis for PLT, PTT, and Fg, no significantly altered result was shown when excluding studies one by one, whether these indicators were examined as dichotomous variables or continuous variables. As for PT, we found that the study by Oertel et al.  accounted for observed heterogeneity. When excluding the study by Oertel et al. , the result for PT as a dichotomous variate was more robust (; 95% CI, 2.47–4.42; ), with no evidence of heterogeneity (; ). As for D-dimer, it was the study by Tong et al.  that brought about the heterogeneity. When excluding the study, the result was more robust (, 95% CI, 6.30–20.00; ), with no evidence of heterogeneity (; ).
High prevalence and mortality highlight the importance of timely prognosis of PHI with good sensitivity and specificity. With repeated CT scanning which is time-consuming and costly, addressing the associations between the abnormal coagulation tests and PHI would be of great avail. So whether coagulopathy correlates with PHI occurrence, which laboratory test is meaningful, and which parameter carries the most weight in predicting PHI become burning questions confronting us.
Our findings showed statistically significant positive associations between PT, D-dimer level, INR, and the risk of PHI after TBI. Higher level of PLT and Fg seemed to suggest a lower risk of PHI. Independent PTT seemed to be of no indicative value. As for dichotomous variables, the contributions to PHI were as follows: DD > INR > PT > Fg > PLT. But when examined as continuous variables, the sequence seemed to be INR > DD > Fg > PLT. Meta-analysis of continuous data was perceived to be more meaningful compared with that of dichotomous data because of less conversion steps to correlation coefficient ().
Meanwhile, there were some discrepancies in association strength between dichotomous and continuous data. Contributions of DD and INR were similar, with INR being a little more influential in the analysis of continuous data, while, as a dichotomous variable, DD had the strongest relationship with PHI. The distinction was speculated to derive from different conversion steps, limited included articles, and subjects. As a dichotomous variate, the predicting value for PT was significant, but that was not the case when it was examined as a continuous variate, which might owe to different test methods of included studies. In analysis for PTT as a dichotomous variate, positive association was detected when ignoring Oertel et al.  or Tong et al. . When D-dimer was modeled as a dichotomous variate, a robust significance was detected, but we only found a marginally significant positive association for it as a continuous variate. Those too few studies were included and internal nonspecificity might bring the divergence. As for Fg, moderate association with PHI was noticed, whether it was examined as a continuous variable or dichotomous variable. Finally, for INR, powerful association with PHI was detected in both data types.
While the quantitative association between coagulative tests and the risk of PHI has been confirmed, we have to acknowledge that four of our included studies are from China and 2 from America. But this does not significantly mean the incidence of ICH in eastern population is higher than in the counterparts, because of lacking in large prospective epidemic studies in our analysis. Potential bias from population difference should be further evaluated through more large epidemic studies.
No meta-analysis about PHI was published before. There is currently 1 publication that we are aware of that has reviewed the current etiology research available to interpret the predictor and mechanism of PHI . In this paper, relationships between PHI and measurable coagulopathy, while clinically useful, were described to be not one of simple cause and effect. Our findings are in agreement with previous articles by Stein et al. , Engström et al. , Schnüriger et al. , and Allard et al. , in which abnormal laboratory test values were independently associated with PHI. In addition, from another perspective, even though PHI was most often diagnosed by the 24-hour CT scan, it might have occurred earlier, preceding and perhaps contributing to the abnormal laboratory tests, which can be regarded as indicators.
Our findings implied that abnormal coagulation tests might indicate occurrence of PHI, which might lead to focused monitoring among TBI patients, and thus save plenty of medical resources. Our interpretation could form the basis for further studies exploring whether correcting these values would prevent PHI and moreover make for subsequent operation. However, there is no strong evidence that correcting laboratorial tests in this situation actually improves outcome. According to Perel et al., there is no reliable evidence from randomized controlled trials to support the effectiveness of hemostatic drugs in reducing mortality or disability in patients with TBI , whereas, in another article, tranexamic acid can reduce all-cause mortality in bleeding trauma patients, with no apparent increase in the risk of vascular occlusive events, if given as early as possible and within three hours of injury, as treatment later than this is unlikely to be effective . Therefore further prospective studies are needed to determine the effects of coagulation-associated therapies in patients with TBI. In any case, however, the correction of abnormal values will indisputably ensure safer operation.
As with all meta-analysis, some caveats are in order. Firstly, bias exists because of defects in study design of included studies and meta-analysis itself, such as publication bias, selection bias, confounding bias, and recall bias. Reporting bias might have also occurred, which derived from the disparities in testing method and cutoff point for each parameter in pertinent studies, which, though moderate, might serve as the confounding factors. We tried our best to minimize the bias by excluding those studies with insufficient patient characteristics [8, 19, 21]. Secondly, the limited literature quantity, which partly comes from inaccurate definitions of PHI, is devoted substantially to the heterogeneities between studies. Thirdly, potential indicators in our meta-analysis were all single parameters, while combined parameters, routinely defined as coagulopathy, may be more powerful in predicting PHI. The criteria of coagulopathy have been changed over time. In 2001, the International Society of Thrombosis and Haemostasis (ISTH) simplified the laboratory diagnosis of DIC . However, only one of our included studies had used this score . More studies on relationship between combined parameters and PHI are suggested here. Fourthly, in most studies, blood sample was tested only once upon admission, with the possibility of potential measurement errors. Therefore, dynamic monitoring of coagulation function should be adopted to ensure convincing results. Finally, suggested definition of PHI in most articles only allowed for a 25% or more increase of bleeding in the subsequent CT scan but does not take the absolute bleeding volume into account. As a consequence, comparability between studies or different subjects becomes questionable.
However, our study had strengths in including relatively newer studies with reliable imaging examinations, quantitative analyses, and precise and consistent definition of PHI as we described above. Moreover, we calculated the comparable association strength in predicting PHI after TBI for each parameter for the first time, which was much more clinically meaningful than the association alone. Thus we could assess the prognostic value of these parameters, which might further guide clinical practices.
Despite the limitations, this meta-analysis has notable clinical and public health implications, which indicate significant inverse associations for PLT level, Fg level, and positive associations for PT, D-dimer level, and INR value in predicting PHI, among which abnormal D-dimer level and INR value were more meaningful. Independent PTT seemed to be meaningless. This study suggests instant test and correction of coagulation parameters at admission to predict PHI and, possibly, better outcome of TBI patients. The focus of our meta-analysis is upon the capability for individual test to predict the presence of PHI after TBI. However, to demonstrate the relationship between coagulopathy and the extent of PHI seems more meaningful, which may be the interest of future studies. Moreover, interrelationships between coagulation tests, which were not discussed here, remain to be unraveled. Eventually, large prospective studies are needed to investigate the underlying pathogenesis better and identify effective therapy to reap the maximum benefits.
Conflict of Interests
No competing financial interests exist.
Danfeng Zhang, Shun Gong, and Hai Jin contributed equally to the paper.
Extra information was supplied here to provide detailed methods so that my procedure could be replicated, which contains detailed search strategy, selection criteria, data extraction and quality assessment and statistical analysis as follows.
- J. A. Langlois, W. Rutland-Brown, and M. M. Wald, “The epidemiology and impact of traumatic brain injury: a brief overview,” The Journal of Head Trauma Rehabilitation, vol. 21, no. 5, pp. 375–378, 2006.
- A. W. Selassie, E. Zaloshnja, J. A. Langlois, T. Miller, P. Jones, and C. Steiner, “Incidence of long-term disability following traumatic brain injury hospitalization, United States, 2003,” Journal of Head Trauma Rehabilitation, vol. 23, no. 2, pp. 123–131, 2008.
- D. J. Thurman, C. Alverson, K. A. Dunn, J. Guerrero, and J. E. Sniezek, “Traumatic brain injury in the United States: a public health perspective,” Journal of Head Trauma Rehabilitation, vol. 14, no. 6, pp. 602–615, 1999.
- S. R. Shackford, R. C. Mackersie, T. L. Holbrook et al., “The epidemiology of traumatic death. A population-based analysis,” Archives of Surgery, vol. 128, no. 5, pp. 571–575, 1993.
- F. Tagliaferri, C. Compagnone, M. Korsic, F. Servadei, and J. A. Kraus, “A systematic review of brain injury epidemiology in Europe,” Acta Neurochirurgica, vol. 148, no. 3, pp. 255–267, 2006.
- W. Rutland-Brown, J. A. Langlois, K. E. Thomas, and Y. L. Xi, “Incidence of traumatic brain injury in the United States,” Journal of Head Trauma Rehabilitation, vol. 21, no. 6, pp. 544–548, 2006.
- S. Sawauchi, K. Taya, T. Hashimoto et al., “Progressive brain injury,” Neurological Surgery, vol. 31, no. 7, pp. 749–755, 2003.
- M. Oertel, D. F. Kelly, D. McArthur et al., “Progressive hemorrhage after head trauma: predictors and consequences of the evolving injury,” Journal of Neurosurgery, vol. 96, no. 1, pp. 109–116, 2002.
- H.-L. Tian, H. Chen, B.-S. Wu et al., “D-dimer as a predictor of progressive hemorrhagic injury in patients with traumatic brain injury: analysis of 194 cases,” Neurosurgical Review, vol. 33, no. 3, pp. 359–365, 2010.
- W.-S. Tong, P. Zheng, J.-S. Zeng et al., “Prognosis analysis and risk factors related to progressive intracranial haemorrhage in patients with acute traumatic brain injury,” Brain Injury, vol. 26, no. 9, pp. 1136–1142, 2012.
- F. Yuan, J. Ding, H. Chen et al., “Predicting progressive hemorrhagic injury after traumatic brain injury: derivation and validation of a risk score based on admission characteristics,” Journal of Neurotrauma, vol. 29, no. 12, pp. 2137–2142, 2012.
- Y. R. Sun, C. H. Xi, E. Wang et al., “Disseminated intravascular coagulation scores as predictors for progressive hemorrhage and neurological prognosis following traumatic brain injury,” Neural Regeneration Research, vol. 6, no. 2, pp. 136–142, 2011.
- C. L. White, S. Griffith, and J.-L. Caron, “Early progression of traumatic cerebral contusions: characterization and risk factors,” The Journal of Trauma, vol. 67, no. 3, pp. 508–515, 2009.
- G. Z. Sanus, T. Tanriverdi, I. Alver, S. Aydin, and M. Uzan, “Evolving traumatic brain lesions: predictors and results of ninety-eight head-injured patients,” Neurosurgery Quarterly, vol. 14, no. 2, pp. 97–104, 2004.
- M. Engström, B. Romner, W. Schalén, and P. Reinstrup, “Thrombocytopenia predicts progressive hemorrhage after head trauma,” Journal of Neurotrauma, vol. 22, no. 2, pp. 291–296, 2005.
- C. B. Allard, S. Scarpelini, S. G. Rhind et al., “Abnormal coagulation tests are associated with progression of traumatic intracranial hemorrhage,” The Journal of Trauma, vol. 67, no. 5, pp. 959–967, 2009.
- S. C. Stein, C. Spettell, G. Young, S. E. Ross, H. H. Kaufman, and L. F. Marshall, “Delayed and progressive brain injury in closed-head trauma: radiological demonstration,” Neurosurgery, vol. 32, no. 1, pp. 25–30, 1993.
- E. F. Chang, M. Meeker, and M. C. Holland, “Acute traumatic intraparenchymal hemorrhage: risk factors for progression in the early post-injury period,” Neurosurgery, vol. 58, no. 4, pp. 647–656, 2006.
- B. Schnüriger, K. Inaba, G. A. Abdelsayed et al., “The impact of platelets on the progression of traumatic intracranial hemorrhage,” Journal of Trauma, vol. 68, no. 4, pp. 881–885, 2010.
- F. Servadei, G. D. Murray, K. Penny et al., “The value of the ‘worst’ computed tomographic scan in clinical studies of moderate and severe head injury. European Brain Injury Consortium,” Neurosurgery, vol. 46, no. 1, pp. 70–77, 2000.
- H. Chen, Y. Guo, S. W. Chen et al., “Progressive epidural hematoma in patients with head trauma: Incidence, outcome, and risk factors,” Emergency Medicine International, vol. 2012, Article ID 134905, 8 pages, 2012.
- T. C. Jeng, M. S. M. Haspani, J. S. Adnan, and N. N. Naing, “Delayed traumatic intracranial haemorrhage and progressive traumatic brain injury in a major referral centre based in a developing country,” Malaysian Journal of Medical Sciences, vol. 15, no. 4, pp. 56–67, 2008.
- Y. R. Yadav, A. Basoor, G. Jain, and A. Nelson, “Expanding traumatic intracerebral contusion/hematoma,” Neurology India, vol. 54, no. 4, pp. 377–381, 2006.
- K. L. Kaups, J. W. Davis, S. N. Parks et al., “Routinely repeated computed tomography after blunt head trauma: does it benefit patients?” Journal of Trauma—Injury, Infection and Critical Care, vol. 56, no. 3, pp. 475–481, 2004.
- F. M. Servadei, A. Nanni, M. T. Nasi et al., “Evolving brain lesions in the first 12 hours after head injury: analysis of 37 comatose patients,” Neurosurgery, vol. 37, no. 5, pp. 899–907, 1995.
- A. Chieregato, E. Fainardi, A. M. Morselli-Labate et al., “Factors associated with neurological outcome and lesion progression in traumatic subarachnoid hemorrhage patients,” Neurosurgery, vol. 56, no. 4, pp. 671–680, 2005.
- S. C. Stein, G. S. Young, R. C. Talucci, B. H. Greenbaum, and S. E. Ross, “Delayed brain injury after head trauma: significance of coagulopathy,” Neurosurgery, vol. 30, no. 2, pp. 160–165, 1992.
- J. P. Broderick, T. G. Brott, J. E. Duldner, T. Tomsick, and G. Huster, “Volume of intracerebral hemorrhage: a powerful and easy-to-use predictor of 30-day mortality,” Stroke, vol. 24, no. 7, pp. 987–993, 1993.
- C. L. Franke, J. C. Van Swielen, A. Algra, and J. Van Gijn, “Prognostic factors in patients with intracerebral haematoma,” Journal of Neurology Neurosurgery and Psychiatry, vol. 55, no. 8, pp. 653–657, 1992.
- The Newcastle-Ottawa Scale (NOS) for assessing the quality of nonrandomised studies in meta-analyses, 2014, http://www.ohri.ca/programs/clinical_epidemiology/oxford.asp.
- J. P. T. Higgins and S. Green, Cochrane Handbook for Systematic Reviews of Interventions, Version 5.0.1, The Cochrane Collaboration, 2011, http://www.cochrane-handbook.org/.
- J. P. T. Higgins, S. G. Thompson, J. J. Deeks, and D. G. Altman, “Measuring inconsistency in meta-analyses,” British Medical Journal, vol. 327, no. 7414, pp. 557–560, 2003.
- D. Kurland, C. Hong, B. Aarabi, V. Gerzanich, and J. M. Simard, “Hemorrhagic progression of a contusion after traumatic brain injury: a review,” Journal of Neurotrauma, vol. 29, no. 1, pp. 19–31, 2012.
- P. Perel, I. Roberts, H. Shakur, B. Thinkhamrop, N. Phuenpathom, and S. Yutthakasemsunt, “Haemostatic drugs for traumatic brain injury,” Cochrane Database of Systematic Reviews, no. 1, Article ID CD007877, 2010.
- I. Roberts, H. Shakur, K. Ker, and T. Coats, “Antifibrinolytic drugs for acute traumatic injury,” Cochrane Database of Systematic Reviews, vol. 12, Article ID D4896, 2012.
- F. B. J. Taylor, C.-H. Toh, W. K. Hoots, H. Wada, and M. Levi, “Towards definition, clinical and laboratory criteria, and a scoring system for disseminated intravascular coagulation,” Thrombosis and Haemostasis, vol. 86, no. 5, pp. 1327–1330, 2001.
Copyright © 2015 Danfeng Zhang et al. This is an open access article distributed under the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.