Skip to main content

Accuracy of intracranial pressure monitoring: systematic review and meta-analysis



Intracranial pressure (ICP) measurement is used to tailor interventions and to assist in formulating the prognosis for traumatic brain injury patients. Accurate data are therefore essential. The aim of this study was to verify the accuracy of ICP monitoring systems on the basis of a literature review.


A PubMed search was conducted from 1982 to 2014, plus additional references from the selected papers. Accuracy was defined as the degree of correspondence between the pressure read by the catheter and a reference “real” ICP measurement. Studies comparing simultaneous readings from at least two catheters were included. Drift was defined as the loss of accuracy over the monitoring period. Meta-analyses of data from the studies were used to estimate the overall mean difference between simultaneous ICP measurements and their variability. Individual studies were weighted using both a fixed and a random effects model.


Of 163 articles screened, 83 compared two intracranial catheters: 64 reported accuracy and 37 drift (some reported both). Of these, 10 and 17, respectively, fulfilled the inclusion criteria for accuracy and zero drift analysis. The combined mean differences between probes were 1.5 mmHg (95 % confidence interval (CI) 0.7–2.3) with the random effects model and 1.6 mmHg (95 % CI 1.3–1.9) with the fixed effects model. The reported mean drift over a long observation period was 0.75 mmHg. No relation was found with the duration of monitoring or differences between various probes.


This study confirms that the average error between ICP measures is clinically negligible. The random effects model, however, indicates that a high percentage of readings may vary over a wide range, with clinical implications both for future comparison studies and for daily care.


Intracranial pressure (ICP) monitoring is widely used in neurointensive care, especially for the management of patients with traumatic brain injury (TBI). ICP levels are used to decide interventions, to verify the efficacy of therapeutic maneuvers, and in formulating a prognosis. For all these purposes accurate measurements are essential.

Clinicians rely on numbers provided by different methods, and generally believe that those numbers reflect actual ICP with a high degree of accuracy. For instance, a recent trial on decompressive craniectomy randomized patients to different treatments when ICP exceeded 20 mmHg [1], assuming that the sensors used ensured a clear-cut threshold.

In real life, however, ICP measurement is challenging. A basic assumption is that the ICP read at one point in the intracranial system properly reflects the average pressure throughout all other locations. Under normal conditions the cerebrospinal fluid (CSF) pressure should in fact be in equilibrium in the whole of the CSF space. Under pathological conditions (as when CSF circulation is obstructed or intracranial masses are expanding), however, ICP cones can develop leading to uneven ICP levels [2, 3]. Even when ICP is homogeneous in the whole intracranial space measurements may not all be accurate, depending on the devices used and the duration of the measurement [46].

Our hypothesis is that clinically used systems measure ICP with different degrees of accuracy, not always providing a precise measure. Therefore, our goal was to evaluate the accuracy and precision over time (drift) of different ICP measurements on the basis of a review of the literature.


Literature search

A PubMed ( search was made, looking for studies published from January 1982 through November 2014. The following keywords were searched: “intracranial pressure” AND “Camino”, “intracranial pressure” AND “Codman”, “intracranial pressure” AND “fluid filled”, “intracranial pressure” AND “tip transducer”, “intracranial pressure” AND “drift”. The search was limited to articles in English and animal studies were included at this stage. Additional articles were screened through the references listed in the papers initially selected.


Accuracy was defined as the degree of correspondence between the pressure read by the catheter and a reference “real” ICP measurement. In order to assess accuracy in vivo, studies comparing simultaneous readings from at least two catheters were included, divided into two groups:

  • Group 1: studies comparing a ventricular fluid-coupled catheter with external transducer (VFC) with another type of device. According to the guidelines of the Brain Trauma Foundation [7], this is the most accurate method for measuring ICP so we took it as the reference standard.

  • Group 2: studies comparing catheters other than VFC.

Some articles included substudies with different sets of paired readings from probes. These were analyzed as separate studies.

Studies on intracranial probes located in the epidural, subdural, or subarachnoid space or comparing infratentorial versus supratentorial probes were excluded from the analysis. Studies were screened for numerical data, and only those reporting the limits of agreement and bias (or data from which they could be calculated) were included. Animal studies were not included in this analysis.

Zero drift

Drift was defined as the loss of accuracy over the monitoring time, a problem related to catheters such as intraparenchymal probes that cannot be re-zeroed during monitoring. In the selected papers drift was assessed by two methods: a) verifying the pressure read by the catheter at atmospheric pressure once it was removed from the patient [8, 9]; and b) measuring pressure changes over time in an artificial hydraulic model [10, 11]. Animal studies were included in this analysis.


Mean ICP differences between the various probes, standard deviation and limits of agreement were reported in most papers. If these summary measures were not available, but mean ICP readings per patient were presented, as read with different probes, we calculated the mean ICP differences and standard deviations (Table 1). Studies for which the results were only given in plots or summary tables were not suitable for the planned analysis, and therefore they were not included on the basis of inadequate data reporting (Fig. 1). The authors of five relevant papers reporting incomplete information [1216] were asked to provide the original data, but this was not accessible (mainly because it was collected decades ago), and these studies were not included either.

Table 1 Main features of the studies included in the meta-analysis
Fig. 1
figure 1

Flow diagram summarizing article selection; 83 articles were identified:64 reported accuracy, 37 reported drift (some reported both). Articles on animals, with probes placed in the epidural, subdural, or infratentorial spaces and with inadequate data reporting were excluded. High-quality articles on drift reported the range, mean and median of drift; the 17 papers refer to 20 studies. High-quality articles on accuracy included comparisons of two ICP probes, with Bland-Altman analysis and adequate data reporting; the 10 papers listed refer to 15 studies

The limits of agreement between simultaneous ICP measurements were calculated using the following formula:

$$ \overline{x}\pm {t}_{\left(0.025,n-1\right)}s\sqrt{1+\frac{1}{n}} $$

where \( \overline{x} \) equals the mean difference, s the standard deviation of the differences, and t(0.025, n–1) the value from Student’s t-distribution corresponding to a two-sided alpha of 0.05 and (n–1) degrees of freedom. While still based on the assumption of normal distribution of probe differences around a mean (“bias” or “offset”), this method compensates for the size of the sample, includes an adjustment for the expected differences in the mean, and it is therefore more widely applicable than the large sample approximation of (\( \overline{x} \) ± 1.96 s).

Meta-analyses of data from the studies were performed to calculate the overall mean difference between simultaneous ICP measurements and the variability. In calculating the overall mean difference across the combined studies, results from individual studies were weighted, assigning the weights using two standard approaches: a fixed effects model and a random effects model.

A fixed effects approach assumes there is one true mean ICP difference between paired probe values. The overall mean difference is calculated by weighting individual study results by the inverse of the observed variance. The random effects approach assumes that the true mean ICP difference between paired probes can vary from one study to another. The overall mean difference is calculated by weighting individual studies according to within-study and between-study variability.

Summary statistical analysis was done using the software program SPSS (Version 21, IBM/SPSS, Inc.) and for meta-analyses we used the software package Comprehensive Meta Analysis (Version 2.2.064, Biostat, Inc.).


The literature search identified 163 studies; 80 were excluded because they were not related to the aim of this study. Of the remaining 83, only 64 reported comparisons of two paired intracranial catheters (Fig. 1).


After studies based on catheters placed in the epidural space, or comparing the infratentorial and supratentorial spaces, or with inadequate data reporting were excluded, 10 articles were left for accuracy analysis (Fig. 1). They reported 15 studies, 10 in Group 1, and 5 in Group 2. The main features of the studies are reported in Table 1, including details on calibration of solid probes before insertion, and zeroing of ventricular fluid-filled catheters. Calibration and/or VFC zeroing maneuvers were reported in the vast majority of Group 1 studies, whereas in Group 2 these maneuvers were less accurately or not reported at all. ICP recordings for individual studies covered a wide range (up to 100 mmHg) and all studies included cases with ICP >20 mmHg. Limits of agreement for individual studies are summarized in Table 2.

Table 2 Limits of agreement of the studies included in the meta-analysis

Both positive and negative differences between probes were observed in individual studies. The combined estimate is a positive difference for probe 1 minus probe 2 readings, partly because of the ordering of the probes in the calculation. All comparisons of the two locations in Group 1 were standardized so that the difference was always parenchymal–ventricular, leaving only one study with negative differences (Table 1). For other paired readings between catheters in similar locations (parenchymal–parenchymal or ventricular–ventricular), the catheter with the highest average reading was identified as probe 1, so as to give consistent positive (and not offsetting) mean differences. The combined mean difference between probes, using a fixed model,was 0.9 mmHg, with a 95 % confidence interval (CI) for the mean of 0.4–1.5 mmHg across Group 1 studies and 1.8 mmHg (95 % CI 1.5–2.2 mmHg) across Group 2 studies. The combined mean difference between all probes, assuming the fixed model, was 1.6 mmHg (95 % CI 1.3–1.9 mmHg) (Fig. 2).

Fig. 2
figure 2

Meta-analysis. Meta-analysis data with the corresponding forest plot for individual data sets (combined Groups 1 and 2). The black horizontal line divides Group 1 (above) from Group 2 (below) studies, as reported in methods. CI Confidence Interval

The combined mean difference between probes, using a random model, was 1.2 mmHg (95 % CI 0.2–2.1 mmHg) in Group 1 studies and 2.3 mmHg (95 % CI 0.5–4.2 mmHg) in Group 2 studies. The combined mean difference between all probes, pooling all studies and assuming the random effects model, was 1.5 mmHg (95 % CI 0.7–2.3 mmHg) (Fig. 2).

Zero drift

The zero drift analysis was reported in 37 articles but only 17 had adequate data reporting (Table 3). Although some papers reported a wide range of values, the mean drift over a long observation period was 0.75 mmHg.

Table 3 Main features of the studies reporting drift

No differences were detected between fiberoptic probes and microstrain-gauge probes (mean fiberoptic 0.59 ± 1.8; mean microstrain-gauge 0.95 ± 0.23; p = 0.8), or between data from clinical and laboratory studies (clinical mean 0.81 ± 0.83; laboratory mean 0.48 ± 0.63; p = 0.82).

Eleven papers addressed the degree of drift as a function of the duration of use; ten found no correlation while one [17] described a weak positive correlation (Spearman’s correlation coefficient 0.342; p = 0.001).


This review found that when two ICP measurements were taken simultaneously using different sensors the averages were close, but with a large standard deviation.

The 10 studies in Group 1 compared various sensors to ventricular catheters. Ventricular catheters are connected through a fluid-filled system (VFC) to an external transducer, which can be zeroed at will, offering a reliable reference standard. The calculation of the average ICP difference in Group 1 included both positive and negative values, which may have reduced the final picture (the absolute difference).

While the majority of studies indicated only small differences between the intraparenchymal probe and the VFC, two reported widely differing ICP levels. Schickner et al. [4] studied 10 patients with refractory ICP. They used a Camino fiberoptic probe, and a ventricular catheter was inserted to drain CSF. The Camino readings, on average, were 9 mmHg higher than the VFC, with single episodes of 40 mmHg difference. Eide et al. [18] retrospectively studied patients after subarachnoid or intraparenchymal bleeding. In five cases a Codman catheter was compared with simultaneous readings by VFC; differences were greater than 10 mmHg in three cases, and one single case had large differences in all measurements, with negative ICP. The authors suggested that significant human errors in zeroing, or sensor damage, may have occurred.

Group 2 comprised five studies comparing parenchymal probes without a ventricular catheter as a standard reference. Often these papers were published in order to prove the existence of ICP gradients, and it is therefore not surprising that they found a striking mean difference [2]. Additionally, in this group all differences were positive, so there were no negative values to offset the final average. This may explain why the mean differences were slightly larger, but still only around 1–2 mmHg.

To sum up all the studies, we used both a fixed model and a random model. Although all the studies involved a comparison of simultaneous ICP measurements, the populations were not homogeneous. They reflected a cross-section of clinical cases, with differences in the manufacturer and type of sensor used, the sensor placement, and the type and extent of brain injury. Since all these factors can potentially affect ICP measurements, it cannot be assumed that all the studies were investigating an unknown but constant difference between paired ICP readings. We therefore feel that the assumptions for the random effects model are more appropriate. Nonetheless, the results with both models were closely comparable.

According to the random model, the combined mean difference between probes was 1.5 mmHg, with a 95 % CI of 0.7–2.3 mmHg. The simple pooled estimate of the standard deviation (unweighted) across the 15 data sets was 4.4 mmHg. Based on this estimate, a future study (similar to the average composition of the 15 studies examined) comparing two simultaneous ICP readings would be expected to have 95 % of the observed differences in the interval 1.5 ± (2 × 4.4) mmHg. Using the random standard error from the meta-analysis, which includes between-study variability, this interval would be slightly higher at 1.5 ± (2 × 5.7) mmHg. According to the random effects model, 70 % of readings could therefore vary in the range of ±6 mmHg, and 95 % of readings in the range of ±11.4 mmHg.

Discrepancies can be “true”, when there are pressure differences in the various areas of the brain, or due to inaccurate readings. True differences, when intracranial gradients are caused by expanding masses or unilateral hemorrhages, call for clinical judgment. In clinical routine, ICP is monitored with a single catheter in the overwhelming majority of patients. In case of unilateral masses with large shift, pressure gradients ( with higher pressure on the lesion side) are possible. In this situation the ICP data have to be interpreted considering where the catheter is placed. Inaccurate readings due to technical problems are more worrying since they are not due to actual intracranial gradients (and cannot be suspected in the computed tomography scan) but to erroneous measurement. Judging from the results of the meta-analysis, true discrepancies are relatively rare, but may be significant, up to ±11.4 mmHg. Clinicians should always carefully analyze the monitored data and also look at trends, possibly in the context of multimodal monitoring.

Fluid-coupled catheters can be re-zeroed as often as necessary while other sensors, in which zeroing cannot be repeated after insertion, may become less precise over time. Zero drift has been reported for several catheters under clinical and laboratory conditions [811, 19]. We found the mean drift was limited (on average less than 1 mmHg); however, single catheters varied widely. In general the pressures were within the limits specified by the manufacturers. There seem to be no significant differences between the various probes in clinical and experimental studies. All papers but one [20] showed no clear correlation between drift and length of ICP monitoring. We can therefore assume that drift is not related to the duration of monitoring, as previously indicated [7].

Our review, pooling different studies often with different designs, has limitations. The bulk of evidence on this topic is also fairly old: the median year of publication of studies on accuracy was 1998, and the range 1992–2012; for studies on drift the median year of publication was 2001 (range 1987–2009). The standards for publication have improved with time, with the result that recent studies provided more comprehensive information compared to the old ones.


The clinical implications of our findings may be relevant both for future comparisons and for daily care. ICP monitoring is widely used to guide diagnostic and therapeutic decisions, so it is essential to know how reliable are the current techniques. The latest update of the Brain Trauma Foundation guidelines [7] concluded that parenchymal transducer devices measure ICP similarly to VFC but have the potential for differences. Our findings confirm that the average error is clinically negligible, but the interval of error is wide.

Key messages

  • A systematic literature review and meta-analysis indicates that the average error between simultaneous ICP measures is small (in the order of 1.5–1.6 mmHg), but in 30 % of readings it could exceed ±6 mmHg

  • When there are intracranial gradients due to expanding masses or unilateral hemorrhages, there are likely to be larger differences between separate ICP measures.

  • In the absence of intracranial gradients, the risk of inaccurate measurement seems rare.

  • These findings are important both for future comparisons studies and for daily care.



Confidence interval


Cerebrospinal fluid


Intracranial pressure


Traumatic brain injury


Ventricular fluid-coupled catheter with external transducer


  1. 1.

    Cooper DJ, Rosenfeld JV, Murray L, Arabi YM, Davies AR, D’Urso P, et al. Decompressive craniectomy in diffuse traumatic brain injury. N Engl J Med. 2011;364:1493–502.

    CAS  Article  Google Scholar 

  2. 2.

    Sahuquillo J, Poca MA, Arribas M, Garnacho A, Rubio E. Interhemispheric supratentorial intracranial pressure gradients in head-injured patients: are they clinically important? J Neurosurg. 1999;90:16–26.

    CAS  Article  Google Scholar 

  3. 3.

    Bekar A, Taskapilioglu O, Yilmazlar S, Ender K, Aksoy K. Is supratentorial pressure difference clinically relevant? Analysis of 55 consecutive cases by bilateral intracranial pressure monitoring. Neurol Res. 2008;30:465–70.

    Article  Google Scholar 

  4. 4.

    Schickner DJ, Young RF. Intracranial pressure monitoring: fiberoptic monitor compared with the ventricular catheter. Surg Neurol. 1992;37:251–4.

    CAS  Article  Google Scholar 

  5. 5.

    Raabe A, Totzauer R, Meyer O, Stockel R, Hohrein D, Schoche J. Reliability of epidural pressure measurement in clinical practice: behavior of three modern sensors during simultaneous ipsilateral intraventricular or intraparenchymal pressure measurement. Neurosurgery. 1998;43:306–11.

    CAS  Article  Google Scholar 

  6. 6.

    Poca MA, Sahuquillo J, Topczewski T, Peñarrubia MJ, Muns A. Is intracranial pressure monitoring in the epidural space reliable? Fact and fiction. J Neurosurg. 2007;106:548–56.

    Article  Google Scholar 

  7. 7.

    Bratton SL, Chestnut RM, Ghajar J, McConnell Hammond FF, Harris OA, Hartl R, et al. Guidelines for the management of severe traumatic brain injury. VII. Intracranial pressure monitoring technology. J Neurotrauma. 2007;24 Suppl 1:S45–54.

    Article  Google Scholar 

  8. 8.

    Koskinen LO, Olivecrona M. Clinical experience with the intraparenchymal intracranial pressure monitoring Codman Microsensor system. Neurosurgery. 2005;56:693–8.

    Article  Google Scholar 

  9. 9.

    Gelabert-González M, Ginesta-Galan V, Sernamito-García R, Allut AG, Bandin-Diéguez J, Rumbo RM. The Camino intracranial pressure device in clinical practice. Assessment in a 1000 cases. Acta Neurochir (Wien). 2006;148:435–41.

    Article  Google Scholar 

  10. 10.

    Morgalla MH, Mettenleiter H, Bitzer M, Fretschner R, Grote EH. ICP measurement control: laboratory test of 7 types of intracranial pressure transducers. J Med Eng Technol. 1999;23:144–51.

    CAS  Article  Google Scholar 

  11. 11.

    Citerio G, Piper I, Cormio M, Galli D, Cazzaniga S, Enblad P, et al. Bench test assessment of the new Raumedic Neurovent-P ICP sensor: a technical report by the BrainIT group. Acta Neurochir (Wien). 2004;146:1221–6.

    CAS  Article  Google Scholar 

  12. 12.

    Sundbӓrg G, Nordström CH, Messeter K, Söderström S. A comparison of intraparenchymatous and intraventricular pressure recording in clinical practice. J Neurosurg. 1987;67:841–5.

    Article  Google Scholar 

  13. 13.

    Chambers IR, Mendelow AD, Sinar EJ, Modha P. A clinical evaluation of the Camino subdural screw and ventricular monitoring kits. Neurosurgery. 1990;26:421–3.

    CAS  Article  Google Scholar 

  14. 14.

    Gambardella G, d’Avella D, Tomasello F. Monitoring of brain tissue pressure with a fiberoptic device. Neurosurgery. 1992;31(5):918–21.

    CAS  Article  Google Scholar 

  15. 15.

    Chambers IR, Kane PJ, Signorini DF, Jenkins A, Mendelow AD. Bilateral ICP monitoring: its importance in detecting the severity of secondary insults. Acta Neurochir Suppl. 1998;71:42–3.

    CAS  PubMed  Google Scholar 

  16. 16.

    Banister K, Chambers IR, Siddique MS, Femandes HM, Mendelow AD. Intracranial pressure and clinical status: assessment of two intracranial pressure transducers. Physiol Meas. 2000;21:473–9.

    CAS  Article  Google Scholar 

  17. 17.

    Stendel R, Heidenreich J, Schilling A, Akhavan-Sigari R, Kurth R, Picht T, et al. Clinical evaluation of a new intracranial pressure monitoring device. Acta Neurochir (Wien). 2003;145:185–93.

    CAS  Article  Google Scholar 

  18. 18.

    Eide PK, Holm S, Sorteberg W. Simultaneous monitoring of static and dynamic intracranial pressure parameters from two separate sensors in patients with cerebral bleeds: comparison of findings. Biomed Eng Online. 2012;11:66.

    Article  Google Scholar 

  19. 19.

    Poca MA, Sahuquillo J, Arribas M, Báguena M, Amorós S, Rubio E. Fiberoptic intraparenchymal brain pressure monitoring with the Camino V420 monitor: reflections on our experience in 163 severely head-injured patients. J Neurotrauma. 2002;19:439–48.

    Article  Google Scholar 

  20. 20.

    Al-Tamimi YZ, Helmy A, Bavetta S, Price SJ. Assessment of zero drift in the Codman intracranial pressure monitor: a study from 2 neurointensive care units. Neurosurgery. 2009;64:94–8.

    Article  Google Scholar 

  21. 21.

    Chambers KR, Kane PJ, Choksey MS, Mendelow AD. An evaluation of the Camino ventricular bolt system in clinical practice. Neurosurgery. 1993;33:866–8.

    CAS  PubMed  Google Scholar 

  22. 22.

    Statham P, Midgley S, Dearden NM, McIntosh C, Miller JD. A clinical evaluation of an intraparenchymal intracranial pressure transducer. In: Avezaat CJJ, Van Eijndhoven JHM, Mass AIR, Tans JTJ, editors. Intracranial Pressure VIII: Proceedings of the 8th International Symposium on Intracranial Pressure. Berlin: Springer-Verlag; 1993. p. 7–10.

    Chapter  Google Scholar 

  23. 23.

    Gopinath SP, Robertson CS, Contant CF, Narayan RK, Grossman RG. Clinical evaluation of a miniature strain-gauge transducer for monitoring intracranial pressure. Neurosurgery. 1995;36:1137–40.

    CAS  Article  Google Scholar 

  24. 24.

    Signorini DF, Shad A, Piper IR, Statham PF. A clinical evaluation of the Codman MicroSensor for intracranial pressure monitoring. Br J Neurosurg. 1998;12:223–7.

    CAS  Article  Google Scholar 

  25. 25.

    Chambers IR, Siddique MS, Banister K, Mendelow AD. Clinical comparison of the Spiegelberg parenchymal transducer and ventricular fluid pressure. J Neurol Neurosurg Psychiatry. 2001;71:383–5.

    CAS  Article  Google Scholar 

  26. 26.

    Lescot T, Reina V, Le Manach Y, Boroli F, Chauvet D, Boch AL, et al. In vivo accuracy of two intraparenchymal intracranial pressure monitors. Intensive Care Med. 2011;37:875–9.

    Article  Google Scholar 

  27. 27.

    Bavetta S, Norris JS, Wyatt M, Sutcliffe JC, Hamlyn PJ. Prospective study of zero drift in fiberoptic pressure monitors used in clinical practice. J Neurosurg. 1997;86:927–30.

    CAS  Article  Google Scholar 

  28. 28.

    Münch E, Weigel R, Schmiedek P, Schürer L. The Camino intracranial pressure device in clinical practice: reliability, handling characteristics and complications. Acta Neurochir (Wien). 1998;140:1113–9.

    Article  Google Scholar 

  29. 29.

    Martínez-Mañas RM, Santamarta D, de Campos JM, Ferrer E. Camino intracranial pressure monitor: prospective study of accuracy and complications. J Neurol Neurosurg Psychiatry. 2000;69:82–6.

    Article  Google Scholar 

  30. 30.

    Citerio G, Piper I, Chambers IR, Galli D, Enblad P, Kiening K, et al. Multicenter clinical assessment of the Raumedic Neurovent-P intracranial pressure sensor: a report by the BrainIT group. Neurosurgery. 2008;63:1152–8.

    Article  Google Scholar 

  31. 31.

    Lang JM, Beck J, Zimmermann M, Seifert V, Raabe A. Clinical evaluation of intraparenchymal Spiegelberg pressure sensor. Neurosurgery. 2003;52:1455–9.

    Article  Google Scholar 

  32. 32.

    Czosnyka M, Czosnyka Z, Pickard JD. Laboratory testing of three intracranial pressure microtransducers: technical report. Neurosurgery. 1996;38:219–24.

    CAS  Article  Google Scholar 

  33. 33.

    Piper I, Barnes A, Smith D, Dunn L. The Camino intracranial pressure sensor: is it optimal technology? An internal audit with a review of current intracranial pressure monitoring technologies. Neurosurgery. 2001;49:1158–64.

    CAS  PubMed  Google Scholar 

Download references


The professional help of Dr. Richard Holcomb for statistical analysis is gratefully acknowledged.

Author information



Corresponding author

Correspondence to Nino Stocchetti.

Additional information

Competing interest

NS received financial support from Orsan Medical Technologies and Johnson & Johnson. The remaining authors declare that they have no competing interests.

Authors’ contributions

Study design: NS. Obtaining funding: NS. Data acquisition (study selection and data extraction): LZ and FDC. Logistical support: NS. Data analysis: NS, SM, ERZ. Manuscript preparation: LZ, SM, NS, FDC, ERZ. All authors read and approved the final manuscript.

Rights and permissions

Open Access This article is distributed under the terms of the Creative Commons Attribution 4.0 International License (, which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made. The Creative Commons Public Domain Dedication waiver ( applies to the data made available in this article, unless otherwise stated.

Reprints and Permissions

About this article

Verify currency and authenticity via CrossMark

Cite this article

Zacchetti, L., Magnoni, S., Di Corte, F. et al. Accuracy of intracranial pressure monitoring: systematic review and meta-analysis. Crit Care 19, 420 (2015).

Download citation

  • Received:

  • Accepted:

  • Published:

  • DOI:


  • Intracranial Pressure
  • Random Effect Model
  • Decompressive Craniectomy
  • Ventricular Catheter
  • Zero Drift