Raised ICT

RESEARCH

        

Diagnosis of elevated intracranial pressure in critically ill adults: systematic review and meta-analysis

Shannon M Fernando,1,2 Alexandre Tran,3,4 Wei Cheng,5 Bram Rochwerg,6,7 Monica Taljaard,3,5 Kwadwo Kyeremanteng,1,5 Shane W English,1,3,5 Mypinder S Sekhon,8 Donald E G Griesdale,8,9,10 Dar Dowlatshahi,3,5,11 Victoria A McCredie,12,13 Eelco F M Wijdicks,14 Saleh A Almenawer,15
Kenji Inaba,16 Venkatakrishna Rajajee,17,18 Je rey J Perry2,3,5

                           

For numbered a liations see end of the article.

Correspondence to:

S M Fernando,
Department of Emergency Medicine and Department
of Critical Care Medicine,
The Ottawa Hospital, Civic Campus, 1053 Carling Avenue, Ottawa, ON K1Y 4E9, Canada sfernando@qmed.ca (or @ shanfernands on Twitter;
ORCID 0000-0003-4549-4289)

Additional material is published online only. To view please visit the journal online.

Cite this as: BMJ 2019;366:l4225 http://dx.doi.org/10.1136/bmj.l4225

Accepted: 30 May 2019

ABSTRACT

OBJECTIVES

To summarise and compare the accuracy of physical examination, computed tomography (CT), sonography of the optic nerve sheath diameter (ONSD), and transcranial Doppler pulsatility index (TCD-PI) for the diagnosis of elevated intracranial pressure (ICP) in critically ill patients.

DESIGN

Systematic review and meta-analysis.

DATA SOURCES

Six databases, including Medline, EMBASE, and PubMed, from inception to 1 September 2018.

STUDY SELECTION CRITERIA

English language studies investigating accuracy of physical examination, imaging, or non-invasive tests among critically ill patients. The reference standard was ICP of 20 mm Hg or more using invasive ICP monitoring, or intraoperative diagnosis of raised ICP.

DATA EXTRACTION

Two reviewers independently extracted data and assessed study quality using the quality assessment of diagnostic accuracy studies tool. Summary estimates were generated using a hierarchical summary receiver operating characteristic (ROC) model.

RESULTS

40 studies (n=5123) were included. Of physical examination signs, pooled sensitivity and speci city for increased ICP were 28.2% (95% con dence

interval 16.0% to 44.8%) and 85.9% (74.9% to 92.5%) for pupillary dilation, respectively; 54.3% (36.6% to 71.0%) and 63.6% (46.5% to 77.8%)
for posturing; and 75.8% (62.4% to 85.5%) and 39.9% (26.9% to 54.5%) for Glasgow coma scale
of 8 or less. Among CT ndings, sensitivity and speci city were 85.9% (58.0% to 96.4%) and 61.0% (29.1% to 85.6%) for compression of basal cisterns, respectively; 80.9% (64.3% to 90.9%) and 42.7% (24.0% to 63.7%) for any midline shi ; and 20.7% (13.0% to 31.3%) and 89.2% (77.5% to 95.2%) for midline shi of at least 10 mm. The pooled area under the ROC (AUROC) curve for ONSD sonography was 0.94 (0.91 to 0.96). Patient level data from studies using TCD-PI showed poor performance for detecting raised ICP (AUROC for individual studies ranging from 0.55 to 0.72).

CONCLUSIONS

Absence of any one physical examination feature is not su cient to rule out elevated ICP. Substantial midline shi could suggest elevated ICP, but the absence of shi cannot rule it out. ONSD sonography might have use, but further studies are needed. Suspicion of elevated ICP could necessitate treatment and transfer, regardless of individual non-invasive tests.

REGISTRATION

PROSPERO CRD42018105642.

Introduction

Elevated intracranial pressure (ICP) is a commonly encountered complication of brain injury,1 and can result in spatial compression, distortion of compartments, and reduced cerebral perfusion pressure. Left untreated, elevated ICP can lead to cerebral ischaemia, brain herniation, and death. Invasive monitoring is the reference standard for measuring ICP,2 3 and sustained values of 20 mm Hg or more have been associated with worse outcomes following traumatic brain injury, subarachnoid haemorrhage, intracerebral haemorrhage, and other conditions.4-7 Therefore, among critically ill patients, considerable attention must be given to monitoring for this possibility. However, the use of ICP monitoring varies substantially worldwide.8

Several clinical practice guidelines indicate that invasive ICP monitoring should be considered in patients in whom there is concern for elevated pressures, or impaired cerebral perfusion.9-11 However, invasive ICP monitoring is not available in all settings (particularly in emergency departments, rural, or resource poor settings) where immediate treatment for elevated ICP might be

WHAT IS ALREADY KNOWN ON THIS TOPIC

Elevated intracranial pressure is a complication of brain injury, including traumatic brain injury, subarachnoid haemorrhage, and intracerebral haemorrhage; le untreated, the condition can lead to cerebral ischaemia, brain herniation, and death

De nitive diagnosis requires placement of an invasive monitor, although this method is associated with complications (including haemorrhage and infection) and is not available in all settings
Therefore, clinicians o en have to rely on non-invasive diagnostic tests, but the accuracy of these tests is unknown

WHAT THIS STUDY ADDS

Independent physical examination ndings (pupillary dilation, posturing, decreased level of consciousness), imaging (compression of basal cisterns, midline shi ), and non-invasive tests had poor accuracy for elevated intracranial pressure

As such, these tests should not be used independently to rule out the condition

High suspicion of elevated intracranial pressure could necessitate treatment and transfer to centres capable of invasive monitor placement

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RESEARCH

       

Visual Abstract Elevated intracranial pressure Effectiveness of non-invasive diagnosis of elevated

Systematic review and meta-analysis intracranial pressure (ICP) in critically ill adults

         

Summary

Data sources Comparison

Results

The interventions had poor accuracy for elevated ICP and should not be used independently to rule out the condition. High suspicion might require transfer to centers capable of ICP monitor placement

    

40 studies   5 123 participants

Interventions

Independent physical examination

Adult patients with brain injury

      

Comparator

     

Imaging

Non-invasive tests

Invasive ICP monitor

Sensitivity (percent, % CI) Specificity

Evidence quality

(GRADE score)

Moderate Low
Low

Moderate Moderate Moderate High

Low Low Low

    

Physical examination signs  Any pupillary dilation
Motor posturing
Glasgow coma scale ≤

Computed tomography signs

Basal cisterns absent or compressed Midline shift > mm
Midline shift > mm
Midline shift > mm

Marshall score ≥ Marshall score ≥ Marshall score ≥

  

 

                                                                                                              

Read the full article online:

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required12; in most centres, only neurosurgeons are trained in ICP monitor insertion.13 Furthermore, the insertion of an ICP monitor is an invasive procedure, and could result in several important complications, including haemorrhage and infection.14 15

As a result, clinicians often use a variety of non- invasive methods to detect raised ICP,16 17 including physical examination and computed tomography (CT) ndings, and their presence is often described as indication for invasive monitoring.9-11 Despite the widespread use of these signs, their diagnostic accuracy for detection of elevated ICP and their correlation with invasive ICP measurement are unknown. Other novel modalities have been suggested for non-invasive measurement of ICP. In a growing body of literature, researchers have investigated the use of sonography of the optic nerve sheath diameter (ONSD) and the use of metrics based on transcranial Doppler (TCD), such as the pulsatility index (TCD-PI).18 19 Given the potential of these bedside tools, better understanding of their diagnostic accuracy is necessary. We conducted a systematic review and meta-analysis with the primary objective of obtaining summary estimates of diagnostic performance (including sensitivity and speci city) of physical examination ndings, CT, ONSD sonography, and TCD for the diagnosis of elevated ICP in critically ill adult patients.

Methods

We structured this systematic review according to PRISMA (preferred reporting items for systematic reviews and meta-analyses) guidelines for diagnostic

test accuracy,20 21 the Cochrane handbook for diagnostic test accuracy,22 and existing guidelines for reviews of diagnostic accuracy.23 The study protocol was registered with the PROSPERO registry (CRD42018105642).

Search strategy

We searched six databases (Medline, PubMed, EMBASE, Scopus, Web of Science, and the Cochrane Database of Systematic Reviews) from inception to 1 September 2018. An experienced health sciences librarian assisted in the development of the search strategy. The search was conducted using the terms “intracranial pressure” and “intracranial hyper- tension” (search strategy shown in supplemental gure 1). We used the Science Citation Index to retrieve reports citing the relevant articles identi ed from our search. We conducted further surveillance searches using the related articles feature.24

Study selection

We included all English language full text articles describing retrospective and prospective observational studies, and randomised controlled trials. We included studies meeting the following criteria: enrolled adult patients (≥16 years); conducted in the emergency department or intensive care unit; and evaluated the test characteristics of physical examination ndings, CT, ONSD (measured 3 mm behind the globe) sonography, or TCD for the diagnosis of elevated ICP. Diagnosis of elevated ICP (reference standard) was de ned by any of the following outcomes: invasive ICP monitor with a pressure reading of 20 mm Hg or more, or craniotomy with operative diagnosis of elevated ICP. We excluded case reports, case series, animal studies, and paediatric studies. Included studies were required to have a 2×2 table of true positive, false negative, true negative, and false positive counts, either extracted from the original article or calculated from other reported information. We also excluded studies where the authors had indicated clinically signi cant latency (de ned as ≥1 hour) between the diagnostic test and the measurement of ICP by invasive ICP monitoring, or if the diagnostic test was conducted after ICP measurement. We emailed authors directly if these values could not be obtained from publications. If the corresponding author did not respond after three attempts, the study was excluded.

We screened studies using Covidence (Melbourne, Australia). In phase one, two reviewers (SMF and AT) independently screened the titles and abstracts of all identi ed studies. In phase two, the same two reviewers independently assessed full texts of the selected articles from phase one. Disagreements were resolved by consensus.

Data extraction

One investigator (SMF) collected the following variables from included articles: author information, year of publication, study design, eligibility criteria, and number of patients. We used a predesigned

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RESEARCH

       

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data extraction sheet (supplemental table 1). Two investigators (SMF and AT) independently collected the true positive, false positive, false negative, and true negative counts. Disagreements were resolved through consensus. All extracted data were veri ed by a third investigator (WC).

Transcranial Doppler indices

In studies investigating the accuracy of TCD-PI, multiple TCD-PI values have been taken from each patient. Therefore, for analysis of TCD-PI, we contacted authors to obtain patient level data. For each patient, we asked for all relevant TCD-PI readings and their corresponding invasive ICP measurement. Receiver operating characteristic curves were generated for each study, and were plotted to determine the appropriateness of pooling the data. Area under the ROC curve (AUROC) for detection of elevated ICP was generated for each study. We also evaluated the AUROC of TCD arterial blood pressure (TCD-ABP) methods, including TCD ow velocities (ICPtcd),25 and the so- called black box mathematical model.26 TCD-ABP methods use changes in cerebrovascular dynamics and non-quantitative cerebral blood ow measures to mathematically estimate ICP.

Quality assessment

Two reviewers (SMF and AT) independently assessed the risk of bias of the included studies, using the quality assessment of diagnostic accuracy studies (QUADAS-2) tool.27 QUADAS-2 assesses four potential areas for bias and applicability of the research question:

• Patient selection: potential risk of bias noted if the evidence indicated veri cation bias (that is, the reference standard was applied on the basis of the index test)

• Index test: potential risk of bias noted if the index test results were interpreted without explicit blinding to reference standard

• Reference standard: potential risk of bias noted if the reference standard could misclassify the target condition

• Flow and timing: potential risk of bias noted if not all patients had the diagnostic test applied using the same criteria, if the diagnostic test was calculated at an inappropriate time interval before de nitive ICP measurement, or if patients were inappropriately excluded.
Studies found to have potential risk of bias for any of these domains were judged as having high risk of bias overall.
Evidence synthesis
For physical examination and CT ndings, we presented individual study results graphically by plotting sensitivity and speci city estimates on one dimensional forest plots (ordered by sensitivity) as well as on the ROC space, to visually assess for heterogeneity. To pool results, we applied the hierarchical summary

ROC model,28 and obtained summary point estimates of the pairs of sensitivity and speci city, as well as diagnostic odds ratios and likelihood ratios, with their 95% con dence intervals. Summary estimates of test accuracy were plotted in the ROC space together with the summary ROC curve. We conducted the analyses using MetaDAS (version 1.3),29 as recommended by the Cochrane handbook for systematic review of diagnostic test accuracy.22 We conducted prede ned sensitivity analyses after excluding studies judged to have potential risk of bias.

Because the diagnostic accuracy of ONSD sono- graphy for prediction of elevated ICP relies on the cuto threshold of continuous ONSD values, bivariate meta- analysis based on the pair of sensitivity and speci city at the optimal cuto value from each study might yield overestimated pooled estimates. The AUROC estimates and the corresponding con dence intervals declared in the original articles were meta-analysed by the Dersimonian-Laird random e ects model30 with Open Meta-Analyst.31

We assessed the overall certainty in pooled diagno- stic e ect estimates using the GRADE (grading of recommendations, assessments, development, and evaluation) approach.32 33 The overall con dence in e ect estimates was categorised as high, moderate, low, or very low. A GRADE evidence pro le was created for each parameter by the guideline development tool (gradepro.org).

Patient and public involvement

No patients were involved in the de nition of the research question, the outcome measures, inter- pretation of results, or manuscript creation. Where possible, the results of this meta-analysis will be disseminated to individual patients and families by the study investigators.

Results

Search results

We identi ed 3779 citations ( g 1). Following the removal of duplicates, 2570 studies were screened, and 47 studies underwent full text review. We included 40 studies in the meta-analysis,34-73 with a total of 5123 patients.

Study characteristics

Study characteristics are displayed in table 1, with

detailed review in supplemental table 2. Of the 40

studies included, 17 (47.9% (n=2456) of patients) were

from North America, 11 (40.0% (n=2071)) were from

Europe, and eight (11.4% (n=586)) were from Asia.

With regards to year of publication, 90.4% (n=4633) of

patients were taken from studies published since 2000,

with 71.8% (n=3679) coming from studies published

since 2010. The most common clinical conditions

were traumatic brain injury (64.5% (n=3304) of patients)34 36 39 40 45 50 53 56 57 58 64-71 and subarachnoid

haemorrhage (14.3% (n=731)).44 55 72 Studies of mixed populations of primary brain injury accounted for

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RESEARCH

        

3779

Records identified through database search, inception to August 2018

condition of elevated ICP, the four studies that used this surgery as a reference standard were considered to have potentially high risk of bias.50 57 68 71 One study used an epidural pressure monitor for the diagnosis of elevated ICP in critically ill patients, and was also considered to have potentially high risk of bias.37 Two other studies were considered to have potentially high risk of bias, because assessors were not blinded to ICP monitor results.43 52

Results of synthesis

Summary estimates of all diagnostic accuracy measures for each physical examination nding and CT nding are displayed in table 2. All summary estimates described are pooled values. GRADE evidence pro les are shown in supplemental tables 3-12.

Physical examination

Only three physical examination ndings had an adequate number of relevant studies for meta-analysis: pupillary dilation,34 45 50-53 56 58 68 71 motor posturing (de ned by Glasgow coma scale motor score ≤3),37 44 45 53 56 58 and decreased level of consciousness (de ned by total Glasgow coma scale ≤8).34 41 50 55 57 58 61 63 65 72 Their forest plots and hierarchical summary ROC curves are shown in supplemental gures 3-5. Presence of pupillary dilation had a sensitivity of 28.2% (95% con dence interval 16.0% to 44.8%) and speci city of 85.9% (74.9% to 92.5%) for the diagnosis of elevated ICP (moderate certainty; table 2). Presence of motor posturing had a sensitivity of 54.3% (36.6% to 71.0%) and speci city of 63.6% (46.5% to 77.8%) for the diagnosis of elevated ICP (low certainty). Finally, a decreased level of consciousness had a sensitivity of 75.8% (62.4% to 85.5%) and speci city of 39.9% (26.9% to 54.5%) for the diagnosis of elevated ICP (low certainty).

Computed tomography

We evaluated multiple CT signs, including absence or compression of basal cisterns,36 57 61 68 70 any midline shift (using either the pineal body or the septum pellucidum as the midline structure),39 42 43 47 52 57 64 69 midline shift more than 5 mm,39 42 43 47 52 57 68 69 72 midline shift more than 10 mm,39 42 43 47 48 52 57 69 and the Marshall classi cation system74 at various thresholds.40 50 63 71 However, no included studies evaluated the sensitivity and speci city of a so-called normal CT, with none of the above signs. Forest plots and hierarchical summary ROC curves are shown in supplemental gures 6-12. Pooled sensitivity and speci city by Marshall Class are shown in supplemental gure 13. Absence or compression of basal cisterns on CT had a sensitivity of 85.9% (95% con dence interval 58.0% to 96.4%; table 2) and speci city of 61.0% (29.1% to 85.6%) for the diagnosis of elevated ICP (moderate certainty). Presence of any midline shift on CT had a sensitivity of 80.9% (64.3% to 90.9%) and speci city of 42.7% (24.0% to 63.7%; moderate certainty). Severe midline shift (that is, >10 mm) had a sensitivity of 20.7% (13.0% to 31.3%) and speci city of 89.2% (77.5% to 95.2%; high certainty).

   

2570

Articles screened

47

1209

Duplicates removed

2523

Articles excluded by title and abstract screening

   

Articles selected for full text review

3 Wrong outcome 2 Wrong population 2 Duplicate

40

Studies included for systematic review analysis

40

Studies included in quantitative synthesis or meta-analysis

Fig 1 | Flowchart summarising evidence search and study selection

18.8% (n=961) of patients.38 42 43 46 49 51 52 54 59 60 63 Two studies exclusively looked at patients with intracerebral haemorrhage,41 48 two enrolled patients with hepatic failure,37 61 and one assessed patients with ischaemic stroke.47

Quality assessment

Quality assessments are summarised in supplemental gure 2. Because evidence of elevated ICP noted during neurosurgery could misclassify the target

 

7

Excluded

       

Table 1 | Characteristics of 40 included studies (n=5123)

Description

No (%) of studies

No (%) of patients

Continent of study

North America

17 (42.5)

2456 (47.9)

Europe

14 (35.0)

2071 (40.0)

Asia

8 (20.0)

586 (11.4)

South America

1 (2.5)

10 (0.2)

Year of publication

1975-79

2 (5.0)

193 (3.7)

1980-89

8 (20.0)

230 (4.5)

1990-99

2 (5.0)

67 (1.3)

2000-09

8 (20.0)

954 (18.6)

2010-18

20 (50.0)

3679 (71.8)

Study design

Prospective cohort

24 (60.0)

2772 (54.1)

Retrospective cohort

15 (37.5)

1986 (38.8)

Randomised controlled trial

1 (2.5)

365 (7.1)

Population

Mixed

12 (30.0)

961 (18.8)

Traumatic brain injury

20 (50.0)

3304 (64.5)

Subarachnoid haemorrhage

3 (7.5)

731 (14.3)

Intracerebral haemorrhage

2 (5.0)

67 (1.3)

Ischaemic stroke

1 (2.5)

25 (0.5)

Hepatic failure

2 (5.0)

35 (0.7)

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Table 2 | Summary estimates of the performance of physical examination and computed tomography ndings for the diagnosis of elevated intracranial pressure

No of patients (No of cohorts)

Sensitivity (%; 95% CI)

Speci city (%; 95% CI)

Diagnostic odds ratio (95% CI)

Likelihood ratio (95% CI)

Positive

Negative

Physical examination signs

Any pupillary dilation

2126 (10)

28.2 (16.0 to 44.8)

85.9 (74.9 to 92.5)

2.39 (1.59 to 3.58)

2.00 (1.44 to 2.78)

0.84 (0.73 to 0.95)

Motor posturing (Glasgow coma scale motor score ≤3)

830 (6)

54.3 (36.6 to 71.0)

63.6 (46.5 to 77.8)

2.08 (1.40 to 3.09)

1.49 (1.17 to 1.90)

0.72 (0.57 to 0.90)

Glasgow coma scale ≤8

2234 (10)

75.8 (62.4 to 85.5)

39.9 (26.9 to 54.5)

2.07 (1.29 to 3.32)

1.26 (1.07 to 1.49)

0.61 (0.43 to 0.85)

Computed tomography signs

Basal cisterns absent or compressed

619 (5)

85.9 (58.0 to 96.4)

61.0 (29.1 to 85.6)

9.55 (1.56 to 56.61)

2.20 (0.99 to 4.93)

0.23 (0.06 to 0.84)

Midline shi >0 mm

627 (8)

80.9 (64.3 to 90.9)

42.7 (24.0 to 63.7)

3.16 (1.43 to 7.01)

1.41 (1.04 to 1.91)

0.45 (0.25 to 0.80)

Midline shi >5 mm

832 (9)

49.4 (34.5 to 64.4)

70.0 (54.9 to 81.8)

2.28 (1.26 to 4.13)

1.65 (1.13 to 2.41)

0.72 (0.56 to 0.93)

Midline shi >10 mm

651 (8)

20.7 (13.0 to 31.3)

89.2 (77.5 to 95.2)

2.16 (0.87 to 5.37)

1.92 (0.87 to 4.25)

0.89 (0.78 to 1.01)

Marshall score ≥3

1316 (4)

80.6 (63.5 to 90.9)

59.9 (40.9 to 76.4)

6.22 (2.55 to 15.22)

2.01 (1.32 to 3.07)

0.32 (0.17 to 0.61)

Marshall score ≥4

1316 (4)

54.2 (37.4 to 70.1)

76.9 (62.6 to 86.9)

3.93 (1.63 to 9.50)

2.34 (1.33 to 4.13)

0.60 (0.41 to 0.87)

Marshall score ≥5

1316 (4)

45.1 (28.5 to 62.8)

83.5 (70.4 to 91.5)

4.15 (1.65 to 10.42)

2.73 (1.40 to 5.31)

0.66 (0.48 to 0.91)

Study

Soliman 2018 Jeon 2017 Robba 2017 Frumin 2014 Raffiz 2012 Rajajee 2011 Moretti 2009 Soldatos 2008 Geeraerts 2007 Kimberly 2007

Overall: P=0.006; I2=60.91%
0.66

Estimate (95% CI)

Estimate (95% CI)

0.88 (0.80 to 0.93)* 0.94 (0.84 to 0.98)* 0.91 (0.88 to 0.94)* 0.87 (0.66 to 0.96)* 0.96 (0.92 to 0.99)* 0.98 (0.96 to 0.99) 0.93 (0.85 to 0.96)* 0.93 (0.79 to 0.98)* 0.96 (0.83 to 0.99) 0.93 (0.84 to 0.98)* 0.94 (0.91 to 0.96)

Sensitivity for elevated ICP decreased from a Marshall Class of at least 3 (80.6%, 63.5% to 90.9%) to at least 5 (45.1%, 28.5% to 62.8%; low certainty). Conversely, speci city increased from a Marshall Class of at least 3 (59.9%, 40.9% to 76.4%) to a Marshall Class of at least 5 (83.5%, 70.4% to 91.5%; low certainty).

Optic nerve sheath diameter

Figure 2 shows a forest plot of AUROC values for the detection of raised ICP by ONSD sonography. Ten studies provided AUROC values for the detection of elevated ICP in a total of 1035 critically ill patients. 38 40 46 49 54 59 60 63 66 67 The pooled AUROC value was 0.94 (95% con dence interval 0.91% to 0.96%, I2=60.9%) for detection of elevated ICP with ONSD sonography. Various ONSD thresholds used across studies, along with corresponding sensitivities and speci cities, are described in supplemental table 13 and supplemental gure 14.

Transcranial Doppler indices

We calculated AUROC values for TCD-PI to detect ICP of 20 mm Hg or more within each study using patient level data35 61 63 73 (794 patients). The ROC curves for individual studies are shown in gure 3, and AUROC values ranged from 0.550 to 0.718, which suggested that pooling patient level data across studies was not appropriate. Three studies evaluated TCD-ABP methods for detection of ICP of at least 20 mm Hg (supplemental gure 15 and supplemental table 14).35 61 62 The pooled AUROC value for detection of elevated ICP with combined TCD-ABP methods was 0.85 (95% con dence interval 0.78 to 0.91, I2=9.6%).

Sensitivity analyses excluding studies with high risk of bias
Results of our sensitivity analyses, after exclusion of studies deemed to have potential high risk of bias, are shown in supplemental table 15 and supplemental gures 16-22. These results did not a ect overall conclusions.

Discussion

We conducted a systematic review and meta-analyses to investigate the accuracy of non-invasive tests for the diagnosis of elevated ICP in critically ill patients, compared with invasive ICP monitoring. Although several studies have failed to identify an optimal strategy for targeted ICP management,75 76 77 78 current guidelines advocate for treatment at an ICP threshold of 20-25 mm Hg.9 79 With the possible complications of invasive monitoring, non-invasive identi cation of patients with elevated ICP is of potential bene t. We found that individual physical examination and CT ndings, in isolation, were not su ciently sensitive for the detection of elevated ICP. Studies investigating sonography of the ONSD used many di erent optimal thresholds for the diagnosis of elevated ICP, with varying degrees of sensitivity and speci city at any speci c threshold. TCD-PI had poor accuracy for the diagnosis of elevated ICP, though other TCD-ABP methods show some promise. Taken together, our study summarises the individual accuracy of non-invasive methods for the diagnosis of elevated ICP.

     

0.74 0.82 0.91 0.99 Area under the ROC curve

Fig 2 | Pooled area under the ROC curve for diagnostic accuracy of sonography of
the optic nerve sheath diameter to detect intracranial pressure of 20 mm Hg or more across studies. *Reported upper limit of 95% con dence interval not symmetrical with the lower limit in the original or logit scale. Therefore, only values with their lower con dence limits were used, and symmetry in the logit scale was assumed for the meta-analysis

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1.0

0.8

0.6

0.4

0.2

0
1.0 0.8

AUROC of pulsatility index

Furthermore, we initially used a broad reference standard that combined invasive ICP measurement or intraoperative evidence of elevated ICP. Intraoperative assessment could misclassify the target condition, although we did a sensitivity analysis after removing these studies, which did not alter our conclusions. Additionally, prevalence of elevated ICP varied between studies, which allowed for the possibility of spectrum bias. Studies with higher prevalence of elevated ICP could be biased towards prioritising and emphasising tests associated with severe or late disease, as opposed to tests that might be more useful for screening a lower risk population. Finally, the threshold for high ICP at 20 mm Hg or higher was an arbitrary choice, because ICP measurement is dynamic and must be interpreted within the clinical context. However, a considerable amount of evidence has linked sustained ICP of 20 mm Hg or higher with poor outcomes, and this value was used most consistently in the literature.

Comparison with other studies

During the initial assessment of patients with brain injury, clinicians usually look for physical examination signs of elevated ICP, including pupillary dilation, motor posturing, and decreased level of consciousness.17 Many have advocated for early ICP management in patients with such signs (especially in the emergency department, or when transfer for de nitive diagnosis and management might be delayed).12 However, certain treatments for high ICP (eg, hyperosmolar treatment) can have adverse e ects.80 We found that none of these classically described physical examination ndings alone was sensitive or speci c enough for the diagnosis of elevated ICP. This shortcoming in diagnostic accuracy is best demonstrated by assessing how pre-test probability is in uenced by the presence or absence of any one of these signs (supplemental table 16). For a patient with a 50% pre-test probability of elevated ICP, the presence of pupillary dilation, motor posturing, or decreased level of consciousness increases the post-test probability to 66.6%, 59.9%, and 55.8%, respectively. Their absence decreases the post-test probability to 45.5%, 41.8%, and 37.8%, respectively. Therefore, the presence of any of these physical signs does not independently indicate elevated ICP. Similarly, absence of any one sign does not adequately rule out elevated ICP. Clinicians without access to any other further methods of testing (eg, in remote or resource poor settings) should not solely rely on these signs to guide initiation of treatment, or the decision to transfer the patient to a more expert centre.

CT ndings are thought to have greater reliability for detecting elevated ICP than physical examination,81 and many studies use CT as the reference standard for elevated ICP. Compression or e acement of the basal cisterns can occur secondary to increased parenchymal oedema, and has long been thought to be a sensitive indicator of elevated ICP.82 83 We found that compression or e acement of basal cisterns had a sensitivity of 85.9%, and a speci city of 61.0%. When evaluated using bayesian principles (supplemental

              

0.6 0.4

Zweifel (2012): 0.608 Cardim (2017): 0.718 Robba (2017): 0.550 Rajajee (2018): 0.588

0.2 0

Specificity

Fig 3 | Generated receiver operating characteristic curves for diagnostic accuracy of transcranial Doppler-pulsatility index for intracranial pressure of 20 mm Hg or more, as based on individual patient level data from four studies. AUROC=area under receiver operating characteristic curve

Strengths and limitations of study

In this review, we used a comprehensive search with clear inclusion and exclusion criteria, examined multiple commonly used methods of ICP measurement, and included unpublished data provided by study authors. We performed individual study risk of bias assessment, and provide sensitivity analyses excluding studies at high risk of bias. We used GRADE methodology to assess and contextualise our ndings based on our overall certainty in e ect estimates.

This review also had some limitations. We evaluated these clinical signs independently, but in clinical practice, providers use a combination of signs to arrive at a diagnosis, and such combinations were not evaluated in the available literature. Ideally, prospective data collection and multivariable regression analysis is required to derive a robust clinical decision instrument based on multiple potential factors in combination. This tool should include important patient factors, such as age and sex, that could modify diagnostic accuracy. Such an instrument should also apply in resource restricted settings, where access to ONSD sonography, TCD, or even CT might not be possible. Additionally, measurement of these diagnostic tests (particularly with relation to physical examination ndings, such as pupillary dilation) could vary between studies. However, although diagnostic tests were conducted in close proximity to the reference standard measurement, most of the included studies did not indicate whether reference ICP values from invasive measurement were based on one point in time, or averaged over an interval, and did not describe time of measurement in relation to any initiated treatment. This lack of clarity in reporting could introduce bias in our analyses.

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table 17), a patient with a 50% pre-test probability of elevated ICP still retains a 18.7% probability despite absence of basal cistern compression or e acement. Therefore, an appreciable number of cases of elevated ICP could be missed if only relying on this sign. Another CT nding that clinicians often consider is midline shift, with worsening shift thought to be associated with higher ICP.81 In our review, the presence of any midline shift only had a sensitivity of 80.9%, an important reminder to clinicians that severe oedema can result in elevated ICP, without evidence of shift on CT. Severe midline shift (that is, >10 mm) had a speci city of 89.2%, but in a patient with a pre-test suspicion of increased ICP of 50%, its presence will only increase post-test probability to 65.8%. Finally, we found that Marshall classi cation was neither sensitive nor speci c, regardless of the threshold used.

Given its increasing use in the clinical setting, we evaluated the accuracy of sonography of the ONSD for detection of elevated ICP.84 However, the varied thresholds used across studies did not allow meta-analysis of sensitivity and speci city at any threshold in our study. The pooled AUROC did suggest high accuracy, although with moderate statistical heterogeneity. Our ndings align with a recent meta- analysis answering the same question, although we included a greater number of studies.85 Despite high pooled AUROC, the variability in thresholds (and sensitivity and speci city at any speci c threshold) suggests that caution should be exercised in the use of ONSD sonography. Its optimised accuracy varies, and no consensus exists on the optimal ONSD threshold to detect elevated ICP. Furthermore, ONSD sonography is often di cult to perform in patients with clinically signi cant facial trauma, and contraindicated in patients with suspected globe injury. Therefore, at present, the use of ONSD sonography for the diagnosis of elevated ICP remains unclear.

Finally, we examined accuracy of TCD-PI using patient level data from four studies. None of the individual studies showed good accuracy for detection of raised ICP, suggesting that TCD-PI might not be useful for this purpose. However, investigation of TCD-ABP methods found relatively stronger accuracy among these methods, including TCD ow velocities and the so-called black box mathematical model. Even though both ONSD sonography and TCD-PI might be immediately available in centres where invasive testing is not, their use for the diagnosis of elevated ICP should be used with caution. Although TCD-ABP methods show promise, particularly to exclude elevated ICP, further research is required. At least one multicentre prospective study of TCD-ABP found a systematic overestimation of ICP.62

While our ndings have obvious value to clinicians who have patients with brain injury, they also have important implications for the development of clinical practice guidelines.86 At present, multiple guidelines advocate for invasive monitoring only in patients with concerning physical examination and

CT signs,9 10 which has resulted in the varied use of invasive monitoring worldwide.8 This study shows that individual physical examination ndings and CT signs are not adequately accurate in the diagnosis of elevated ICP, although we were unable to examine the accuracy of combinations of ndings, as found in many current guidelines. Our study suggests that decisions related to the use of monitoring should not simply be restricted to any one speci c physical examination or CT criterion, but rather a more comprehensive view should be taken, focusing on patient factors, factors related to the brain injury, as well as clinical signs.87 Given the potential role for ICP monitoring to improve outcomes by avoiding further brain injury due to high pressures, understanding its potential breadth of use has important implications in the care of critically ill patients.79 For clinicians caring for these patients (particularly in resource limited settings), high suspicion of elevated ICP shouldpromptconsiderationofempiricaltreatment, as well as invasive ICP monitoring, or transfer to a capable centre.

Conclusions and policy implications

Our systematic review and meta-analyses found that individual physical examination signs were not su ciently sensitive for the diagnosis of elevated ICP. CT ndings (namely, e acement of basal cisterns) had better diagnostic accuracy, but are not readily available in all centres. ONSD sonography could be an accurate method of measuring ICP, but no agreed threshold exists, and the method’s accuracy can be in uenced by provider expertise. Therefore, providers should exercise caution in interpretation of any ndings derived from ONSD sonography. TCD-PI had poor performance, but TCD-ABP methods might be promising for diagnosing elevated ICP, although further validation is required. Given the available evidence, clinicians must take a comprehensive view of patients with primary brain injury, and should consider empirical treatment followed by invasive monitoring (or transfer to a capable centre) if they have any clinical concerns for increased ICP.

AUTHOR AFFILIATIONS

1Division of Critical Care, Department of Medicine, University of Ottawa, Ottawa, ON, Canada

2Department of Emergency Medicine, University of Ottawa, Ottawa, ON, Canada

3School of Epidemiology and Public Health, University of Ottawa, Ottawa, ON, Canada

4Department of Surgery, University of Ottawa, Ottawa, ON, Canada

5Clinical Epidemiology Program, Ottawa Hospital Research Institute, Ottawa, ON, Canada

6Department of Medicine, Division of Critical Care, McMaster University, Hamilton, ON, Canada

7Department of Health Research Methods, Evidence, and Impact, McMaster University, Hamilton, ON, Canada

8Department of Medicine, Division of Critical Care Medicine, University of British Columbia, Vancouver, BC, Canada

9Centre for Clinical Epidemiology and Evaluation, Vancouver Coastal Health Research Institute, Vancouver, BC, Canada

10Department of Anesthesiology, Pharmacology, and Therapeutics, University of British Columbia, Vancouver, BC, Canada

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11Divison of Neurology, Department of Medicine, University of Ottawa, Ottawa, ON, Canada

12Interdepartmental Division of Critical Care, Department of

Medicine, University of Toronto, Toronto, ON, Canada

13
Toronto Western Hospital, University Health Network, Toronto, ON,

Canada

14Division of Neurocritical Care and Hospital Neurology, Department of Neurology, Mayo Clinic, Rochester, MN, USA

15Division of Neurosurgery, Department of Surgery, McMaster University, Hamilton, ON, Canada

16Division of Acute Care Surgery, Department of Surgery, University of Southern California, Los Angeles, CA, USA

17Department of Neurology, University of Michigan, Ann Arbor, MI,

USA

18
Department of Neurosurgery, University of Michigan, Ann Arbor,

MI, USA

We thank Ian Ball, Danilo Cardim, Nicolas de Riva, Jacob Pace, Chiara Robba, and Christian Zweifel for providing primary data that allowed for completion of meta-analyses.

Contributors: SMF, AT, and JJP conceived the study idea. SMF, AT, WC, BR, and JJP coordinated the systematic review. SMF and AT designed the search strategy, screened abstracts and full texts, acquired
the data, and judged risk of bias in the studies. WC performed the data analysis. BR created the GRADE evidence pro les. All authors interpreted the data analysis and critically revised the manuscript. All authors had the opportunity to review the nal manuscript, and provided their permission to publish the manuscript. All authors agree to take responsibility for the work. SMF is guarantor. The corresponding author attests that all listed authors meet authorship criteria, and that no others meeting the criteria have been omitted.

Funding: None received.

Competing interests: All authors have completed the ICMJE uniform disclosure form at http://www.icmje.org/coi_disclosure.pdf and declare: no support from any organisation for the submitted work; no nancial relationships with any organisations that might have an interest in the submitted work in the previous three years; no other relationships or activities that could appear to have influenced the submitted work.

Ethics approval: Not applicable.
Data sharing: The Meta-DAS SAS macro (recommended by the

Cochrane handbook for systematic reviews of diagnostic test accuracy) is available at https://methods.cochrane.org/sdt/ so ware-meta-analysis-dta-studies and is also available from the corresponding author.

The lead author a rms that the manuscript is an honest, accurate, and transparent account of the study being reported; that no important aspects of the study have been omitted; and that any discrepancies from the study as planned have been explained.

This is an Open Access article distributed in accordance with the Creative Commons Attribution Non Commercial (CC BY-NC 4.0) license, which permits others to distribute, remix, adapt, build upon this work non-commercially, and license their derivative works on di erent terms, provided the original work is properly cited and the use is non-commercial. See: http://creativecommons.org/licenses/ by-nc/4.0/.

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