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Clinical and economic evaluation of modulated electrohyperthermia concurrent to dose-dense temozolomide 21/28 days regimen in the treatment of recurrent glioblastoma: a retrospective analysis of a two-centre German cohort trial with systematic comparison and effect-to-treatment analysis
  1. Sergey V Roussakow
  1. Galenic Research Institute, Moscow, Russia
  1. Correspondence to Dr Sergey V Roussakow; roussakow{at}


Objective To assess the efficacy and cost-effectiveness of modulated electrohyperthermia (mEHT) concurrent to dose-dense temozolomide (ddTMZ) 21/28 days regimen versus ddTMZ 21/28 days alone in patients with recurrent glioblastoma (GBM).

Design A cohort of 54 patients with recurrent GBM treated with ddTMZ+mEHT in 2000–2005 was systematically retrospectively compared with five pooled ddTMZ 21/28 days cohorts (114 patients) enrolled in 2008–2013.

Results The ddTMZ+mEHT cohort had a not significantly improved mean survival time (mST) versus the comparator (p=0.531) after a significantly less mean number of cycles (1.56 vs 3.98, p<0.001). Effect-to-treatment analysis (ETA) suggests that mEHT significantly enhances the efficacy of the ddTMZ 21/28 days regimen (p=0.011), with significantly less toxicity (no grade III–IV toxicity vs 45%–92%, p<0.0001). An estimated maximal attainable median survival time is 10.10 months (9.10–11.10). Cost-effectiveness analysis suggests that, unlike ddTMZ 21/28 days alone, ddTMZ+mEHT is cost-effective versus the applicable cost-effectiveness thresholds €US$25 000–50 000/quality-adjusted life year (QALY). Budget impact analysis suggests a significant saving of €8 577 947/$11 201 761 with 29.1–38.5 QALY gained per 1000 patients per year. Cost-benefit analysis suggests that mEHT is profitable and will generate revenues between €3 124 574 and $6 458 400, with a total economic effect (saving+revenues) of €5 700 034 to $8 237 432 per mEHT device over an 8-year period.

Conclusions Our ETA suggests that mEHT significantly improves survival of patients receiving the ddTMZ 21/28 days regimen. Economic evaluation suggests that ddTMZ+mEHT is cost-effective, budget-saving and profitable. After confirmation of the results, mEHT could be recommended for the treatment of recurrent GBM as a cost-effective enhancer of ddTMZ regimens, and, probably, of the regular 5/28 days regimen. mEHT is applicable also as a single treatment if chemotherapy is impossible, and as a salvage treatment after the failure of chemotherapy.

  • recurrent glioblastoma
  • modulated electro-hyperthermia (meht)
  • oncothermia
  • dose-dense temozolamide (ddtmz
  • effect-to-treatment analysis (eta)
  • cost-effectiveness analysis

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Strengths and limitations of this study

  • The study first introduces the application of a novel clinical analysis called effect-to-treatment analysis.

  • The study applies a systematic comparator in the form of the pooled average of a meta-analysis of a systematic review of comparable trials.

  • The study includes comprehensive economic evaluation, comprising consistent costs analysis, cost-effectiveness analysis, budget-impact analysis and cost-benefit analysis.

  • Because the study is based on a single retrospective trial, future studies are needed to confirm its findings.


Glioblastoma multiforme (GBM) is a common and aggressive primary brain tumour, accounting for 45%–54% of all adult gliomas.1 2 Despite the recent treatment advances, GBM prognosis remains dismal, with the median survival time (MST) limited to 15–18 months.3 The prognosis for patients with recurrent GBM remains poor, with the MST between 3 and 6 months.4 As 20 years ago, treatment of recurrent GBM can be considered successful if the stable disease is achieved.5

Standards of care are not yet defined for recurrent GBM.6 Treatment options at recurrence include surgical resection, re-irradiation and chemotherapy (CTX),7 although all of these options have significant limitations.8 The standard CTX treatment for recurrent GBM, based on the milestone European Organisation for Research and Treatment of Cancer/National Cancer Institute of Canada Clinical Trials Group (EORTC/NCIC CTG) trial,9 10 includes oral DNA-alkylating agent temozolomide (TMZ) given daily at 150–200 mg/m2 for 5 days in each 28-day cycle (5/28 d) (Stupp regimen).3 Unfortunately, TMZ adds only about 2.5 months to the MST compared with RT alone at first-line treatment.9 10 Given that >50% of patients fail to respond to TMZ treatment over 6–9 months, and the majority (60%–75%) of patients with GBM who do not have a methylated O6-methylguanine-DNA methyltransferase (MGMT) promoter derive limited benefit from TMZ treatment,11 and 15%–20% of patients treated with TMZ develop clinically significant toxicity,8 TMZ should be considered a modestly effective chemotherapy. Attempts to improve the Stupp regimen involve, among others, the increased TMZ dosage, known as dose-dense TMZ (ddTMZ) regimens.12

The rationale for ddTMZ is based on the known role of specific DNA repair enzyme 7MGMT in tumour resistance to alkylating agents such as TMZ. MGMT effectively recovers TMZ-related DNA damage. Methylation of the promoter region of the MGMT gene suppresses MGMT expression. A methylated MGMT promoter is observed in 30%–60% of GBMs.13 Because MGMT is a suicide enzyme and requires resynthesis for recovery of its enzymatic activity,14 it can be depleted by continuous alkylating pressure. Therefore, prolonged exposure and higher cumulative doses of TMZ could sensitise tumours to the alkylating damage, with toxicity as a natural limiter of such dose escalation. Some ddTMZ regimens were applied versus the standard 5/28 d regimen, including the 7/14 d (7 days on/7 days off), 21/28 d and continuous administration (7/7 d or 28/28 d) regimes.12 15 Multiple single-armed and retrospective studies of ddTMZ at recurrent GBM showed progression-free survival at 6 months (PFS-6m) ranging from 19% to 44% and an MST of 7–10 months.12 However, a recent phase III randomised controlled trial (RTOG 0525)16 of ddTMZ 21/28 d versus the standard 5/28 d adjuvant regimen for newly diagnosed patients with GBM after completion of concurred chemoradiotherapy (CRT), failed to show an advantage of ddTMZ in MST (14.9 vs 16.6 months in the standard arm, p=0.63), although it did show an improvement of PFS-6m (6.7 vs 5.5 months) with borderline significance (p=0.06), with somewhat higher toxicity in the ddTMZ arm. Therefore, the efficacy of ddTMZ regimens remain unproven.12

Finally, it should be noted that the modern chemotherapies like TMZ, bevacizumab and other antiangiogenic agents are not cost-effective.17–20 In fact, there remains a significant unmet need for more effective treatments of high-grade gliomas,21 and the poor outcomes of the current treatment of recurrent GBM requires novel approaches.5

There is a physical technology called modulated electrohyperthermia (mEHT, oncothermia), the effectiveness of which was demonstrated in many phase I/II trials in recurrent brain gliomas,22–26 and also in cancer of lung,27–30 liver,31–33 pancreas,34 35 cervix,36 37 breast,38oesophagus,39 colorectal cancer,40–43 malignant ascites44 and soft tissue sarcomas.45 46 Clinically, mEHT is typically used as an enhancer of radiation27 36 and chemotherapy, although it possesses its own effectiveness of at least a similar magnitude to these treatments.23 40 47

mEHT is a novel method of treatment of solid malignant tumours by the local application of a high-frequency electromagnetic field (13.56 MHz), modulated by 0–5 kHz flicker noise, by virtue of impedance-coupled functionally asymmetric electrodes.48 mEHT is positioned as a next-generation hyperthermic technology based on the selective heating of intercellular compartments of tumour tissue and cell membranes, instead of the heating of a bulk volume of the tissue, as the conventional temperature-dependent hyperthermia (HT) does.49–53

Unlike the old HT technologies, mEHT transfers the focus from the dielectric heating (field effect) to the Joule (electric) heating in order to improve focusing and penetration depth. Since the current has a known ability to concentrate in areas with a higher conductance,54 and the increased conductance is one of the basic properties of malignant tissue,55 a tumour is a natural concentrator of electrical current. This feature has long been used for electrical impedance scanning56 and current-density imaging.57 58 The penetration depth of current in the impedance-matched system is 20–25 cm59 vs 14–18 cm only60 in the regular capacitive HT at 13.56 MHz. Therefore, the emphasis on the current allows transferring energy selectively to the tumour for any depth and with minimal losses. ‘Electrohyperthermia’ means predominantly electric heating.61

A combined set of technical solutions is used to achieve maximal electrical heating: namely, the impedance matching based on the phase angle between voltage and current; functionally asymmetric electrodes, providing the necessary stability of the field and size difference-dependent amplification of the current; physiologic skin cooling, minimising skin losses at energy transfer and a ‘skin sensor’ concept, which allows for refuse thermometry without detriment to safety.48 ‘Free of thermometry’ use is a great advantage of mEHT, abolishing the labour-intensive thermometry planning, installation and control, thus drastically reducing time and costs, minimising side effects and significantly improving the perception of the treatment by a patient.62

The electric heating creates quasi-stable local thermal gradients at the nano level (eg, transmembrane thermal gradient63), which are maintained by the balance of continuous delivery of energy by external field and energy dissipation by natural cooling mechanisms, mainly by a blood flow.64 65 Thus, the nanoheating, depending on the field power applied and physiological cooling power displayed, can develop even without macroscopic heating.66 It was shown ex vivo that a 42°C temperature in mEHT is only responsible for 25%–30% of the total antitumour effect and a slightly smaller effect was shown in the case of normothermia.67 Thus, the effect of mEHT is thermally induced but not temperature-dependent.68

The clinical value of the not temperature-dependent effects can no longer be questioned after the Food and Drug Administration approval69 of tumour-treating fields (TTF), an athermal technology using continuous impact of a low-intensity (0.7–1 V/cm) alternating electromagnetic field with a frequency of 100–200 kHz through insulated scalp cross-sectional electrodes.70–75 In a phase III study,76 TTF displayed the same efficacy at recurrent GBM as the best physician choice CTX (MST 6.6 vs 6.0 months, respectively (p=0.27)) with better quality of life.

Nevertheless, mEHT usually causes hyperthermia-range heating77–80 in accordance with a classical maxima of Schwan on the impossibility to reach significant ‘non-thermal’ effects without substantial heating.81 The effect of mEHT is power-dependent but not signal-dependent. It is not connected with multiple tiny and questionable processes such as demodulation and molecular energy uptake82 (although we cannot completely exclude these possibilities). The power range of mEHT (0.2–2 W/cm2) is far above the ‘thermal noise limit’ of 0.01 W/cm2.83

Fractal modulation is a specific feature of mEHT. The carrying frequency is amplitude-modulated by ‘pink noise’ (1/f),84 which is typically emitted by all self-organised living systems and reflects their fractal organisation.85 Since a malignancy always losses organisation, it more or less emits ‘red’ or Brownian noise (1/f2)86 (correctly speaking, its noise spectrum is more ‘reddish’). Fractal modulation allows for increasing specific absorption of modulated field energy in the ‘red noise’ sites, selectively amplifying the effect of mEHT.87 Also, the noise can amplify cancer-specific frequencies88 by ‘stochastic resonance’.89 It is reported in vitro that modulation can amplify the effect of mEHT by 20%–50%.87

An important feature of mEHT is its selectivity, both macroscopic and cellular. Macroscopic selectivity of tumour heating is based on the automatic impedance-based autofocusing of electric current in the tumour.54 The cellular selectivity of mEHT, based on the membrane selectivity and modulation, was demonstrated in vitro using a mixed culture of cancerous and normal cells. mEHT selectively destroyed malignant cells without damage to the normal cells, and the extent of the damage was proportional to the degree of malignancy.90

The exact mechanism of mEHT action is unknown. Both temperature-dependent and -independent mechanisms are among possible options. Temperature-dependent mechanisms include disorder of tumour blood flow, oxygen and glucose deprivation, depletion of intracellular ATP, the influx of sodium and depolarisation of cellular membrane91–93 and acidification.94–96 Since these effects are present in all HT applications, and they do not lead to results characteristic for mEHT, we propose that there must be other mEHT-specific mechanisms of action. Many not temperature-dependent (so-called ‘non-thermal’) effects are reported to have a peak at about 10 MHz, namely direct bactericidal effect and enhancement of antibiotics action (bioelectric effect), both in bacterial films97 and planktonic phase98; dielectrophoresis,99 damage of mitochondrial function100 and destruction of lysosomes.101

Although the frequency and field strength (2–5 V/cm) applied in mEHT cannot cause a significant change in the membrane potential,102 there are many reasons to suggest a specific membrane-acting effect of mEHT. The 10 MHz is a relaxation frequency of the β-dispersion range (0.1–100 MHz) caused by Maxwell-Wagner relaxation of cell membranes,103 which means a peak of membrane dielectric loss and selective membrane excitation (heating) at this frequency104 (reorientation of protein-bound water molecules, the motion of polar protein subgroups, the Maxwell-Wagner relaxation of the cell interior or the additional Maxwell-Wagner relaxations due to the non-spherical cell shape, also contribute to the β-dispersion103), and also a peak of phase shift of membrane polarisation under the effect of the external alternative field, which nearly reaches a quadrature (−80°).102 The relaxation frequency of the reorientational proton motion of water-bound proteins also peaks at about 10 MHz (range 1–100 MHz).105

Another possible effect of mEHT is an arrest of cell division with possible mitotic catastrophe,98 attributable to a subcellular ponderomotoric effect (dielectrophoretic forces suppress the assembly of the mitotic spindle71), to membrane polarisation (cell division phases are associated with changes in membrane potential, and non-linear processes of hyperpolarisation and depolarisation, under the effect of radiofrequency (RF) field, suppress proliferation72) or to resonance phenomena.106 Also, effects on the cytoskeleton107 108 and selective activation of some enzymes, both conformational and voltage-dependent (in the case of membrane enzymes),109 are reported.

The overall effect of mEHT is connected with an extracellular expression of intracellular signalling molecules of cellular stress (eg, heat shock proteins (HSP) and p53 protein),110 which unmask cancer cells and initiate the immune response and apoptosis.111 It has been shown in vivo and in vitro that the antitumour effect of mEHT is mainly connected with significant activation of apoptosis, which develops over 72 hours after a single impact.111–113 Some immune-dependent effects are reported, namely the abscopal effect,114 115 which is considered as a basis for a ‘RF vaccination’.116 117 Expression of many immune-specific pathways has been reported in vitro in mEHT.111 118–120 Overexpression of cell-junction proteins with the significant restoration of intercellular junctions, which can contribute to the induction of apoptosis,121 122 and reorganisation of cytoskeleton107 are reported for mEHT.

Taking into account the extensive and long-term (since 1996) successful application without any negative report, a systematic review of results of mEHT is possible and necessary. Collecting the data for the systematic review and meta-analysis on the mEHT treatment of brain gliomas, we asked for raw data whenever possible. The raw data of the trial by Sahinbas et al 23 including 155 patients with high-grade gliomas (HGG) were obtained on request. After analysis of the data, some shortcomings were revealed, namely duplications, incorrect grouping by histology and incorrect calculation of survival function in view of incorrect processing of censoring. After corrections and recalculation, the results of this trial appeared so interesting that we believe they deserved to be republished. In this retrospective analysis, we report the result of the systematic clinical comparison and economic evaluation of mEHT concurrent to the ddTMZ 21/28 d regimen in the treatment of recurrent GBM. No change to the raw data was made.

Materials and methods


The objective of this study is to assess the efficacy and cost-effectiveness of mEHT concurrent to ddTMZ 21/28 d regimen versus ddTMZ 21/28 d alone in patients with recurrent GBM.

Questions of the study

  • Does mEHT significantly enhance the ddTMZ 21/28 d regimen?

  • Is the addition of mEHT to ddTMZ 21/28 d regimen cost-effective?

Trial design

This retrospective clinical and economic evaluation is based on a systematic comparison and effect-to-treatment analysis (ETA) of a retrospective, single-arm study23 (study of interest (SOI)) performed in two German centres (the Gronemeyer Institute of Microtherapy at the University of Bochum and the clinic ‘Closter Paradise’, Soest) between 2000 and 2005.

Inclusion and exclusion criteria

Patients with relapsed or progressed after incomplete resection or progressive inoperable histologically confirmed GBM or gliosarcoma (WHO IV), having undergone a complete conventional first-line and second-line pretreatment were selected. From those, patients treated with ddTMZ 21/28 d in combination with mEHT (with or without supportive therapy but without re-irradiation, resurgery or other chemotherapy), were selected. No exclusion criteria were applied.


Survival was the main outcome of the study:

  • MST is the time from the initial event to the moment when the value of cumulative survival function (Kaplan-Meier estimate (KME)) reaches 50%. Here, the term MST is applied to survival since relapse/progression or the date of the first mEHT session, while survival since the date of diagnosis is defined as median overall survival time.

  • Overall survival (OS) is the value of cumulative survival function (KME) at the set time moments from the date of the initial event.

  • OS time is the time from the initial event to the death of any reason.

No surrogate outcomes were used.


The studied intervention was a combination of ddTMZ 21 days on, 7 days off regimen (100 mg/m2/day) with concurrent mEHT as an enhancer (ddTMZ+mEHT). MEHT (the intervention of interest (IOI)) was applied using an EHY2000 device (Oncotherm Kft, Hungary) with 2 days intervals between sessions (on each third day) concurrent with TMZ and afterwards, for up to 3 months. A dose-escalating scheme was used with a gradual increase of power from 40 to 150 W and increase of time from 20 to 60 min, during 2 weeks, adding modulation from the second week (figure 1). Then, a step-up heating was applied, increasing the power from 60 to 150 W during 60 min sessions, to ensure tumour temperature of >40°C during 90% of the treatment time. Dose escalation was limited by patient’s individual tolerance. The mEHT course was considered low-dose (LD-mEHT), if did not exceed eight complete 60 min sessions. Supportive and alternative treatments (SAT) included Boswellia caterii extract 6 g/day three times daily to be taken orally, mistletoe extract 15 ng/day subcutaneously 3 times/week, and selenium 300 µg/day orally, for 3 months.

Figure 1

Dose-escalating scheme of modulated electrohyperthermia. The tenth session attains the maximum escalation, the further sessions are the same.

Response and survival assessment

The objective response was assessed according to the MRI McDonald criteria.123 Survival function was assessed by the Kaplan-Meier estimate. Survivors were right-censored on the date of completion of the study (30 May 2005), lost patients were censored on the date of the last contact and excluded patients were left-censored on the date of diagnosis/enrolment.

Statistical methods

Statistical analysis was performed using the built-in Excel 2016 analysis package using the methods of descriptive statistics, correlation and regression analysis. Normality of distribution was estimated by the Kolmogorov-Smirnov test. CIs of medians were calculated according to Conover,124 relative risks (RR) and ORs according to Altman,125 risk difference (RD) according to Newcomb and Altman,126 product of means according to Goodman,127 ratio of means according to Fieller128 129 for independent means, and by Taylor approximation130 for dependent means, and the ratio of two independent lognormally distributed estimates by Newcomb’s MOVER-R algorithm.131 Inverse-variance weighting was used.132 The significance of differences in parametric criteria was estimated by the two-sample Student’s t-test or Welch t-test for unequal variance133; and for paired non-parametric criteria (proportions) by the Pearson’s χ2 test according to Campbell-Richardson.134 The significance of rates and proportions with known 95% CI was estimated according to Altman and Bland,135 and the significance of the difference of two independent estimates by the two-sample z-test. All p values are two-sided. A 95% probability (α=0.05) was used for significance testing. Since log-transformation significantly inflates CIs (up to 40-times in some cases136), 90% probability (α=0.1) is considered applicable for the significance of the difference of estimates based on log-transformed parameters in some cases.

Survival analysis was performed using the Excel-based software package GRISA (Galenic Research Institute, 2015) by KME of the cumulative probability of survival.137 SEs and CIs of KME were estimated by Greenwood’s formula,138 and the significance of differences by the log-rank test.139 The hazard function was estimated by the Cox proportional hazards regression model.140

Meta-analysis was performed using the Excel-based software package GRIMA (Galenic Research Institute, 2015) according to Borenstein et al 132 and statistical algorithms of the Cochrane Collaboration.141 The heterogeneity of studies was assessed by the I2 criterion.142 In view of the significant heterogeneity of the cohorts, a random effects model was applied.

Effect-to-treatment analysis

ETA was performed according to our own algorithm143 with the following settings: a unit of treatment is a 28-day cycle, and the parameter of comparison is the mean survival time (mST) after relapse. Here, we use mST for mean survival time and MST for median survival time. Medians were transformed into means with 95% CI using the algorithm by Hozo et al 144 for medians with range and our own simplified algorithm (see online supplementary 1) for medians with 95% CI. The life months gained (LMG) parameter was calculated by subtracting the expected mST (emST). Effect-to-treatment ratio (ETR) was calculated by dividing the LMG by the mean number of cycles (mNC). Life quality adjustment was not possible due to significant initial differences between the cohorts. The median ETR (METR) was estimated by attenuation of the ETR according to the formula: Embedded Image , where CA is a coefficient of attenuation. The dependence of mST from mNC was estimated by the function Embedded Image , where NC is a serial number of cycle; the extremum of the function is a maximal attainable survival time (MAST), the abscissa of the extremum is a peak number of cycle (PNC). Cost-effective number of cycles (CENC) was estimated as abscissa of cost-effective survival time value (CEST=95% MAST). Cycles needed to treat per LMG (CNTM) was estimated as the reciprocal of the difference of Embedded Image . The effect enhancement ratio (Embedded Image ) was estimated as an auxiliary parameter for calculation of CI and significance of CNTM: since EER and CNTM use the same parameters with the same null hypothesis [Embedded Image ], their CIs and significance are the same, and these parameters can be easily calculated for EER according to Altman and Bland.135

Supplementary Material

Supplementary data

Economic evaluation

For economic evaluation, cost-effectiveness analysis (CEA) with sensitivity analysis, budget impact (BIA) and cost-benefit (CBA) analyses were performed.145–149 CEA and BIA were performed from the perspective of a health provider. CEA was based on the cost-utility ratio (CUR) and incremental cost-effectiveness ratio (ICER). The ratio of CURs (CURR) and increment of CURs (ICUR) were used to compare CURs. The proportion of cost-effective cases (%CE) was estimated by one-tailed directional integral z-test with the null hypothesis [Embedded Image ], where CET is a cost-effectiveness threshold. To estimate a sensitivity of CEA, a multiparametric equal cost-effectiveness test was performed exploring the value of a key parameter in which the value of CURR equals 1.0 (or ICUR=0). The BIA estimated the difference of costs for treatment of 1000 patients per year. CBA estimated the total economic effect (saving and earnings before interest and taxes (EBIT)) from the perspective of a healthcare facility.


SOI is reported according to the STROBE (Strengthening the Reporting of Observational studies in Epidemiology) statement for reporting observational studies.150 Economic evaluation is reported according to the CHEERS (Consolidated Health Economic Evaluation Reporting Standards) standards.151


Patients’ flow

A total of 153 patients with different brain tumours (box) were enrolled in the two centres between 2000 and 2005 (figure 2). Of those, 138 patients had primary brain tumours, and 87 were graded as WHO IV, including 81 GBM and one gliosarcoma (n=82). Of those, 76 patients were adults (>20 years). Fifty-eight adult patients with GBM received a combination treatment (mEHT±ddTMZ±RT±SAT), other 18 patients with GBM were treated with mEHT only (with or without SAT). Twenty-three patients of the combination cohort were younger than 50 years and received high-dose (HD) mEHT (HD-mEHT). The cohort of interest (COI) included 54 patients who received mEHT+ddTMZ (with or without SAT). Four other patients of the combination cohort received RT in addition to mEHT, either alone (n=1) or with ddTMZ (n=3) (with or without SAT). Of the adult patients with GMB (n=76), 24 received LD-mEHT and 52 received HD-mEHT; 59 received SAT vs 17 who did not.


Histological types of brain tumours (SOI)

Total patients: 153

  • (C71) Malignant neoplasm (MN) of brain: 137

    • WHO II: 8

      • Astrocytoma: 4

      • Mixed glioma: 4

    • WHO III: 39

      • Astrocytoma: 34

      • Mixed glioma: 3

      • Ependimoma: 1

      • Oligodendroglioma: 1

    • WHO III–IV: 4

      • Astrocytoma: 3

      • Infratentorial glioma: 1

    • WHO IV: 87

      • Glioblastoma: 81

        • Age >20 years: 75

        • Age <20 years: 6

      • Gliosarcoma: 1

      • Medulloblastoma: 3

      • Primitive neuroectodermal tumour: 1

  • (D43.1) Neoplasm of uncertain behaviour of brain, infratentorial: 1

  • (C79.3) Secondary MN of brain and cerebral meninges: 15

    • Adenocarcinoma: 12

      • MN of breast: 7

      • MN of bronchus and lung: 3

      • MN of colon: 1

      • MN of pancreas: 1

    • Ewing sarcoma: 1

    • Malignant rhabdoid tumour: 1

    • Cancer of unknown primary: 1

Figure 2

CONSORT flow chart. White: COI, cohort of interest; light grey: CSA, cohorts of covariate survival analysis; dark grey: cohorts out of analysis; black: analyses; ddTMZ, dose-dense temozolomide; GBM, glioblastoma; mEHT, modulated electrohyperthermia; SAT, supportive and alternative treatments.

Patients’ characteristic

Fifty-four adult patients with WHO IV GBM (n=53) and gliosarcoma (n=1) matched the inclusion criteria (COI). The mean age was 48.7±1.5 years (median, 49.8 years; range 25.9–68.2; 95% CI 42.2 to 52.8), including 2 (4%) elderly patients (≥68 years) and 26 patients (48%) over 50 years. Thirty-three patients were males and 21 females (table 1).

Table 1

Patients’ characteristic

Forty-two (78%) patients underwent complete trimodal pretreatment including surgery and chemoradiation, four (7%) received previous surgery and radiation, four (7%) received surgery and chemotherapy, three (6%) received only radiation and one (2%) received only chemoradiation. By modalities, 50 (93%) patients underwent previous surgery, 50 (93%) radiation and 47 (87%) chemotherapy (mainly TMZ). The characteristics of the other cohorts are given in table 1.

Details of treatment

All patients (100%) in the COI received ddTMZ+mEHT treatment, and 43 (80%) patients received concurrent SAT (table 2).

Table 2

Details of treatment

In total, 84 ddTMZ cycles were performed for 54 patients, an average of 1.6±0.1 cycles per patient (median 1.0 cycles; range 1.0–5.0; 95% CI 1.0 to 1.0). The average duration of the treatment was 2.7±0.6 months (median 1.1 months; range 1 day to 26.4 months; 95% CI 0.8 to 1.5 months). In eight (15%) cases, the treatment was terminated because of progressive disease. The average time elapsed since primary diagnosis to the first mEHT session was 12.9±2.1 months (median 9.5 months; range 0.2–94.2; 95% CI 5.9 to 10.7). A total of 995 mEHT sessions were performed, with a mean of 18.4±0.4 per patient (median 14; range 3–65; 95% CI 10 to 17). There were 18 (33%) patients with LD-mEHT.


Fifteen patients (28%) in the COI were assessed for a response (figure 2). One patient (7%) showed a complete response (CR) and two (13%) showed a partial response (PR) so that the objective response rate was 20% (table 3).

Table 3

Survival and response rates (COI)

Five patients (33%) showed stable disease and seven (47%) were in progressive disease status, giving a beneficial response rate (BRR) of 53% (see the section ’Bias assessment and limitations of the study').


All of the patients of the COI were included in the survival analysis (figure 2). Average follow-up since the first mEHT session was 8.4±1.2 months (median 6.0 months; range 0.7–47.3 months; 95% CI 4.6 to 7.5 months). Average follow-up since the last mEHT session (table 3) was 5.6±1.1 months (median 3.5 months; range 1 day to 46.4 months; 95% CI 2.2 to 5.3 months). For that period, 36 (67%) patients died, 2 (4%) were lost (censored) and 16 (30%) were alive at the end of the follow-up period (right-censored). The MST since the first diagnosis was 20.8 months (95% CI 15.2 to 25.1) and the 5-year OS was 13.5% (95% CI 1.0% to 26.0%). The MST since the first mEHT session was 7.7 months (95% CI 5.7 to 9.4). Survival since the first mEHT session at 12 and 24 months was 29.5% (95% CI 15.5% to 43.6%) and 18.8% (95% CI 6.5% to 33.1%), respectively (figure 3) (see the section ’Bias assessment and limitations of the study').

Figure 3

Kaplan-Meier survival function of the patients treated with ddTMZ+mEHT (n=54) since diagnosis (A) and since first mEHT session (A1). C, censored; ddTMZ, dose-dense temozolomide; mEHT, modulated electrohyperthermia; S, survival function.


Unfortunately, the raw data presented does not contain safety data, so we rely on the safety data of the 140 patients reported in the primary paper.23 No grade III–IV toxicity was reported. Short-term (<2 hour) asthenia after treatment was encountered in 10% of the cases, rubor of the skin in 8%, oedema of fresh scars in <1%, subcutaneous fibrosis in 1%, burning blisters grade I–II in 2% and headache, fatigue and nausea (1–2 days) in 12% (see the section ’Bias assessment and limitations of the study').

Analysis of the results

Covariates survival analysis

There was no difference in survival between patients treated with mEHT only (with or without SAT) and with the combination treatment (table 3, figure 4), neither by survival (MST since first mEHT 6.4 months (95% CI 3.1 to 9.9) vs 7.7 months (5.8 to 9.5), p=0.403) or by response (BRR 57% vs 53%, p=0.77), although the mEHT-only regimen was applied to significantly older patients (median 59.1 vs 49.8 years in the combination treatment sample, p=0.037) with KPS <60% unfit for chemotherapy and radiation.

Figure 4

Survival (Kaplan-Meier estimate) since first mEHT session of ‘mEHT-only’ (A, n=18) and combination treatment (B, n=58) samples. α, probability of type I error; C, censored; mEHT, modulated electrohyperthermia; P, p value; S, survival function.

However, we did detect a significant difference between samples with LD-mEHT and HD-mEHT, both in survival since first mEHT (p=0.007; HR 2.19; 95% CI 1.21 to 3.95) and response (p=0.003) (table 4, figure 5). A similar pattern was shown in the analysis of the sample treated with SAT versus the sample without SAT (figure 6): the MST since first mEHT was 8.7 months (95% CI 7.2 to 11.4) with SAT vs 2.9 months (95% CI 2.3 to 5.5) only without SAT (p=0.004, HR 0.40 (95% CI 0.36 to 0.45)) (see the section ’Discussion').

Figure 5

Survival (Kaplan-Meier estimate) since first mEHT session of patients treated with low-dose mEHT (A, n=24) and high-dose mEHT (B, n=52). α, probability of type I error; C, censored; mEHT, modulated electrohyperthermia; P, p value; S, survival function.

Figure 6

Survival (Kaplan-Meier estimate) since first mEHT session of patients with SAT (A, n=59) and without SAT (B, n=17). α, probability of type I error; C, censored; mEHT, modulated electrohyperthermia; P, p value; S, survival function; SAT, supportive and alternative treatments.

The sample of younger patients (<50 years) with HD-mEHT treatment showed the best results (figure 7): an MST since diagnosis of 23.9 months (95% CI 13.0 to not attained); a 5-year OS of 31.0% (95% CI 5.1 to 56.8); an MST since first mEHT session of 12.8 months (95% CI 8.2 to 48.1) and a BRR of 85.7%. Although the OS did not differ significantly from the complete sample (p=0.32), the survival since first mEHT and BRR were significantly better (p=0.047 and p=0.007, respectively).

Figure 7

Survival (Kaplan-Meier estimate) since first mEHT session of all patients with GBM (A, n=76) and younger (<50 years) patients with high-dose mEHT (B, n=23). α, probability of type I error; C, censored; mEHT, modulated electrohyperthermia; P, p value; S, survival function.

Systematic comparator

Based on a systematic review152 and a narrative review12 of different ddTMZ regimens, five phase II, cohort, uncontrolled clinical trials addressing the ddTMZ 21/28 d regime were identified (table 4).

Table 4

Comparison of dose-dense temozolomide trials: patients’ characteristic

The Italian trial of Brandes et al 153 studied a highly selected group of CTX-naïve patients with good performance status (median KPS=90%). This was a specific design aimed to study the efficacy of TMZ at GBM recurrent in TMZ-naïve patients, and, due to this specificity, the results of Brandes et al are incomparable to both the current trial and the all other four ddTMZ trials, all made on TMZ-pretreated patients with KPS 60%–80%. The US trial by Norden et al 154 is another standalone trial with a median KPS of 90% and an extremely high share (65%) of patients with a methylated MGMT promoter (excluded from the comparison, see the section ’Bias assessment and limitations of the study'). The German trial by Strik et al 155 also stands alone: despite the worst patients’ performance status (median KPS=60%, which is usually considered unfit for CTX), the patients received the extensive course of ddTMZ (a median of five cycles; mean 7.3) with a modest toxicity. Two other studies, a Turkish study by Abacioglu et al 156 and a Spanish study by Berrocal et al 157 were the real-world19 studies without an obvious difference from everyday practice, although the trial by Berrocal et al claims to have selected TMZ-resistant patients, its findings do not differ from those of the trial by Abacioglu et al both by extent of TMZ pretreatment (median of six cycles) or by the time elapsed since diagnosis (14 vs 13 months).

The details of patients’ characteristic and treatment schedules are presented in table 4. The response and survival data are presented in table 5.

Table 5

Comparison of dose-dense temozolomide trials: response and survival

The survival data by Strik et al were corrected because the originally reported survival in months was derived from weeks by the division to 4 (eg, 32.8 weeks=8.2 ‘chemo months’), which overrated survival by an average of 9%.

Effect-to-treatment analysis

We used ETA to compare the trials according to the principles described in the ‘Statistical Methods’ section. The mST after relapse in patients receiving standard modern treatment (which can be defined as trimodal first-line and second-line treatment approximately equal to Stupp protocol9 was the parameter of comparison. Since the expected (reference) value of mST is absent in the literature, we deducted it from the available data as 4.775 months (95% CI 3.9 to 5.6) (see online supplementary 2). Taking into account the worst MST of the study by Berrocal et al (5.1 months (95% CI 3.7 to 8.5)), this MST expectancy seems reasonable. For the further analysis, we considered this parameter as emST since relapse (in view of supposed normal distribution according to central limit theorem). For further comparisons, meta-analysis and economic evaluations, the median parameters of all trials (MST and number of cycles) were translated into means according to the ‘Statistical methods’ section.

Supplementary Material

Supplementary data

The results of ETA show the advantage of the mEHT+ddTMZ regimen. The main comparator was the weighted average of three ddTMZ trials with comparable samples (weighted average (WA) (2–4)) (table 6).

Table 6

Effect-to-treatment analysis: basic parameters

The WA of all ddTMZ studies (WA (1–4)) and standalone studies by Brandes et al and Strik et al were the additional comparators.

The mST in the mEHT+ddTMZ sample (7.625±0.57 m) was ranked third after the cohorts by Brandes et al and Srtik et al, and was significantly better than in the trial by Berrocal et al (5.6±0.73 m, p=0.031) and worse than in the sample by Brandes et al, with borderline significance (9.95±1.13 m, p=0.070); other differences were not significant (table 6). The differences by LMG were not significant. The mNC in the mEHT+ddTMZ sample (1.56±0.13) was significantly less compared with all cohorts and WAs (p≤0.004). The relative survival gain changes the ranking: ddTMZ+mEHT provided significantly better ETR (ETR=1.83 LMG/ccl (95% CI 1.04 to 4.20)) compared with all other cohorts and WAs (p<0.022), except the cohort by Brandes et al (ETR=1.13 LMG/ccl (95% CI 0.72 to 1.80), p=0.273).

To make ETRs comparable, the common denominator was estimated as a median of the mean number of cycles of all of the cohorts: median number of cycles (MNC)=4.2 cycles. To lead ETRs to the common denominator, attenuation modelling was performed in the range of CA 10%–25%×ccl-1 (table 7).

Table 7

Effect-to-treatment analysis: 15% attenuation model estimation

A CA level of 15% was chosen for the following analysis as an optimal prognosis (figure 8A). According to this scenario, the median ETR (METR) of the ddTMZ+mEHT cohort is 1.19 LMG/ccl (95% CI 0.59 to 2.40), which is significantly more than the METR of the main comparator (METR=0.57 LMG/ccl (95% CI 0.39 to 0.85), p=0.011) and other cohorts (p≤0.016), except that of the cohorts by Brandes et al (METR=1.20 LMG/ccl (95% CI, 0.74 to 1.95), p=0.979) and Strik et al (METR=0.81 LMG/ccl (95% CI 0.44 to 1.48), p=0.302). This scenario means that the ddTMZ+mEHT cohort would have to reach the maximal attainable survival time (MAST) of 10.10 months (95% CI 9.10 to 11.10) at the sixth cycle, which is significantly more than the MAST of the main comparator (7.34 months (95% CI 6.46 to 8.21), p<0.001) and other cohorts (p≤0.015), except the cohort by Brandes et al (10.15 months (95% CI 9.24 to 11.06), p=0.943).

Figure 8

Effect-to-treatment analysis, attenuation modelling. (A) CA=15.0%; (B) CA=19.3%. CA, coefficient of attenuation; MNC, median number of cycles; mNC, mean number of cycles; mST | ETR: dot, mean survival time, ETR, line segment effect-to-tretament ratio.

Based on the CNTM criterion (table 7), the ddTMZ+mEHT regimen displayed strong and significant benefit versus the cohorts by Berrocal et al and Abacioglu et al and both WAs (CNTM=1.00–1.68 ccls/LMG, p<0.016), moderate and insignificant benefit versus cohort by Strik et al (CNTM=2.64 ccls/LMG, p=0.302) and no effect versus the cohort by Brandes et al (CNTM=−90.98 ccls/LMG, p=0.979).

Thus, our ETA suggests a strong and significant enhancement of the ddTMZ 21/28 d regimen by concurrent mEHT.

Sensitivity analysis

Sensitivity analysis was completed to validate the robustness of the ETA results. For this purpose, the lower and upper limits of CA were estimated (figure 8, table 8).

Table 8

Effect-to-treatment analysis: sensitivity analysis

The lower limit of CA=15% is defined by the cohort by Abacioglu et al, in which the ascending mST reaches a CEST level (6.98 months) with other cohorts being between CEST and MAST (figure 8A); the upper limit at CA=19.3% is defined by the cohort by Strik et al, in which the descending mST reaches CEST=8.35 months (figure 8B). The CNTM of the ddTMZ+mEHT cohort versus the main comparator attenuates from strong to moderate from the lower to the upper limit (from 1.62 to 2.14 ccls/LMG), but remains significant (p=0.011–0.018). The extremum modelling shows that the CNTM of the ddTMZ+mEHT cohort versus the main comparator remains significant (p≤0.05) up to CA=24.4%. Thus, the result of the ETA is robust.

Safety comparison

The ddTMZ+mEHT regimen did not display any grade II–IV toxicity, whereas the ddTMZ regimens generated such toxicity events at a rate of 45%–92%, the difference was always highly significant (p<0.001) (table 9).

Table 9

Comparison of dose-dense temozolomide trials: adverse events

Grade I–II toxicity in the ddTMZ+mEHT cohort was mild. Since 4% of grade I nausea can be attributed to TMZ, total 30% of the mEHT-related events encountered. The main of them are grade I–II skin reactions (12%) and grade I short-term (<2 hours) post-treatment asthenia (10%).

Economic evaluation

Cost-effectiveness analysis

CEA was performed from the perspective of a health provider with a lifetime horizon. The goal of the CEA was to evaluate the cost-effectiveness of the ddTMZ+mEHT regimen versus ddTMZ only, so that only the direct costs for these two modalities were analysed. It was considered by default that other costs are dispensed proportionally and do not affect the estimation based on the direct costs (see the section ‘Bias assessment and limitations of the study’).

Two costs models were used for the CEA: conditionally termed ‘German’ and ‘US’ (see the section ‘Discussion’). The German model has lower costs and less variance compared with the US model. For both the models, end user prices for TMZ were estimated based on open sources (as at 21 January 2017): mean US$1.70/mg (95% CI 1.44 to 1.95) in the USA158 and €1.14/mg (95% CI 1.12 to 1.17) in Germany.159

The cost of the single mEHT session varies between countries, from $100 in Russia to $500 in Israel and South Korea (as at 2016). In the European Union, it varies in the range from €145.14 per session in Germany to €300–€400 in private clinics outside Germany. From the perspective of a health provider, this cost is limited by national regulations: for example, one deep HT session is reimbursed at a rate of €173 in Italy (National tariff nomenclature code 99.85.2) and €145.14 in Germany (GOA code 5854). In those countries where HT is not reimbursed by the health insurance system (eg, Spain and Austria), the median private cost is about €300.

Thus, from the perspective of a health provider, the mean cost of a single mEHT session in Germany was estimated as €145.14 with zero variance (95% CI €145.14 to €145.14), whereas in the USA the estimated mean is US$300 (95% CI US$234 to US$366) (table 10).

Table 10

Calculated prices for economic evaluation

The results of the CEA are presented in table 11 (German model) and table 12 (US model).

Table 11

Cost-effectiveness analysis (German model)

Table 12

Cost-effectiveness analysis (US model)

Along with four single cohorts of comparison, three WA were assessed. WA (1–4) combines all the cohorts, WA (2–4) excludes the cohort by Brandes et al as a selected cohort (selection bias-free average), WA (2–3) also excludes the cohort by Berrocal et al in view of its very low survival gain, which significantly affected the final results (low-result bias-free average, the main comparator).

The mean costs of ddTMZ+mEHT regimen both in the German (€9344 (95% CI 9199 to 9488)) and US (US$15 378 (12 703 to 18 052)) models were significantly less versus all cohorts and WAs (p<0.05 in all cases). The cohort by Abacioglu et al displayed the lowest costs (€14379 (95% CI14071 to 14687)) and US$21 325 (95% CI 18 135 to 24 515), respectively) and the cohort by Strik et al the highest (€31 539 (95% CI 30 863 to 32 215) and US$46 775 (95% CI 39 779 to 53 772)); the main comparator WA (2–3) costs were calculated to be €18 138 (95% CI 17 750 to 18 527) and US$26 901 (95% CI 22 877 to 30 925)).

For estimation of the CUR, we used the weighted average index of health-related quality of life of all five cohorts (0.74 quality-adjusted life year (QALY)/LY) to counterweight the initial difference of the samples (range of median KPS 60%–90%) not connected with the treatment (table 1).

The CUR of the ddTMZ+mEHT regimen, both in the German (€19 871/QALY (95% CI 17 719 to 22 024)) and the US (US$32 704/QALY (95% CI 27 215 to 38 193)) models was also less versus all comparators. The difference was highly significant (p≤0.001), except for the cohort by Brandes et al (€24 292/QALY (95% CI 20 263 to 28 321)), p=0.061 and US$36 028/QALY (95% CI 28 866 to 43 189), p=0.472). The main comparator WA (2–3) was calculated as €40 424/QALY (95% CI 36 758 to 44 091) and US$59 954/QALY (95% CI 51 427 to 68 481), p<0.001 for both.

In the German model, versus CET €25 000/QALY (%CE25k) and €30 000/QALY (%CE30k), the %CE for the ddTMZ+mEHT regimen was 88.8% (%CE25k) and 99.2% (%CE30k) (ie, it was cost-effective vs both CETs). All the other comparators showed negligible %CE (0%–2.5%), except the cohort by Brandes et al, which was also mainly cost-effective at both CETs (%CE25k = 53.6% and %CE30k = 76.5%). In the US model, versus CETs US$30 000/QALY (%CE30k) and US$50 000/QALY (%CE50k), the %CE for the ddTMZ+mEHT regimen was 4.5% (%CE30k) and 94.6% (%CE50k) (ie, it was cost-effective vs CET=US$50 000 only). Two other cohorts were also mainly cost-effective versus CET=US$50 000: namely the cohorts by Brandes et al (%CE50k = 84%) and Abacioglu et al (%CE50k = 51.3%); the %CE50k of all of the WAs was negligible (2.0%–2.3%).

As for comparative cost-effectiveness, only the cohort by Brandes et al showed an ICER of less than the applied CETs (€28 706/QALY (95% CI −5 529 to 62 940) and US$34 727/QALY (95% CI −12 095 to 81 549). All of the other cohorts and WAs were not cost-effective with the ICER ranging from €43 717/QALY/US$55 827/QALY to €367 368/QALY/US$519 683/QALY.

Sensitivity analysis

The sensitivity of the CEA was analysed by using an equal cost-effectiveness test, that is, by exploring the value of a key parameter in which the value of the relative CUR (CURR) of the ddTMZ+mEHT regimen and the main comparator (WA (2–3)) equals to 1.0 (or ICUR=0). For this purpose, the following variables were tested: the price of the mEHT session; the number of TMZ application days (days on) over a 28 days cycle; the price of TMZ; the number of cycles of ddTMX+mEHT.

The equivalent price of the mEHT session is €683 in the German model, and US$1013 in the US model and the coefficient of reliability of the CEA result (CR, the ratio of a key parameter of CE-equivalent model and the standard model) is 3.4/4.7 (table 13).

Table 13

Cost-effectiveness analysis: sensitivity analysis

The equivalent price of TMZ is US$0.50/mg in the US model and €0.24/mg in the German model; once again with CR=3.4/4.7. Since these key parameters (prices) do not affect the treatment efficacy, their equivalent values do not need any size-dependent correction. The result means that the ddTMZ+mEHT regimen is cost-effective in the entire range of possible prices with double to quadruple redundancy.

The equivalent number of TMZ ‘days on’ is 4.46 days in the German model and 6.21 days in the US model, once again with CR=3.4/4.7. This time, the key parameter affects the treatment efficacy, because the diminished dose (days) of ddTMZ can decrease the effectiveness and, therefore, can increase the ddTMZ+mEHT/ddTMZ CURR and cause an offset of the equivalence point to the lower values of ‘days on’. This means that the ddTMZ+mEHT regimen, most probably, keeps the cost-effectiveness up to the standard 5/28 d regimen and below it, and the cost-effectiveness of mEHT could be generalised for the entire range of TMZ treatment of recurrent gliomas.

The maximal equivalent number of ddTMZ+mEHT cycles is 2.86 in the US model and 3.17 cycles in German model (CR=1.8/2.1). This key parameter also affects the treatment efficacy, because, with an increase of cycle number of the ddTMZ+mEHT regimen, the treatment efficacy and CUR will rise with an offset of the equivalence point towards the longer course. At the least, this result means that the length of the ddTMZ+mEHT regimen can be doubled without loss of cost-effectiveness.

Thus, the sensitivity analysis confirms that the results of the CEA are remarkably stable, with double to quadruple redundancy.

Budget impact analysis

We estimated a budget impact of the treatment of 1000 patients per year (tables 11 and 12) with a time horizon of 1 year; versus the main comparator, the saving (ΔC1000) is €8 794 882/US$11 523 498 per year (German/US model) with 29.1 years of survival gain (∆E1000). The average saving ranged from €8 577 947/US$11 201 761 to €8 794 882/US$11 523 498 with 29.1–38.5 QALY gained. To extrapolate the economic results to a larger time horizon, the depreciation rate of 20% per year must be applied.

Cost-benefit analysis

CBA was performed from the perspective of a large neurooncology centre treating >150 patients with recurrent GBM per year (table 14, table 15).

Table 14

Cost-benefit analysis (US model)

Table 15

Cost-benefit analysis (German model)

The main assumptions of the CBA are as follows: mean sessions per patient is equal to that of SOI; the mEHT device does not generate revenues other than healthcare system reimbursement for the treatment of those patients; the mEHT device operates in 12 hours/day mode; the capital costs including acquisition costs, shipment, installation and training are €300 000 in the German model and US$400 000 in the US model; the service costs rate is 12% of the capital costs per year with 2-year free of charge guarantee service; the depreciation of the mEHT equipment at a rate of 15% per year; the norm of profit of the healthcare provider is 50% (operational costs are 67% of revenues); the saving obtained as a result of the introduction of the ddTMZ+mEHT regimen depreciates at a rate of 20% per year; the saving is not included in EBIT; no price discount/inflation rate is used; the time horizon is 8 years.

Our CBA shows that use of an mEHT device is profitable with the above parameters and generates the total revenues in amount of €3 124 574/US$6 458 400 with EBIT €210 525/US$1 044 800 per mEHT device over 8 years, provided that operational costs are €2 083 049/US$4 305 600 for that period (€260 381/US$538 200 per year). With respect to the saving due to the use of the ddTMZ+mEHT regimen instead of ddTMZ only, the total economic effect (saving+EBIT) over the 8-year period is €5 700 034/US$8 237 432 per mEHT device.


Clinical evaluation

In a general comparison, the ddTMZ+mEHT cohort has revealed a non-significantly better mean survival time (mST=7.63 months (95% CI 6.52 to 8.74)) compared with the main comparator, the pooled mST of three trials on TMZ-pretreated patients (7.16 months (95% CI 6.25 to 8.08), p=0.531).

Covariates survival analysis has revealed the comparable efficacy of mEHT and ddTMZ, at least in weakened patients (figure 4), suggesting the feasibility of mEHT as a single treatment in those patients, for which CTX is impossible in view of toxicity or bad performance. The advantage of mEHT over chemotherapy was shown elsewhere in GBM22 and other cancers.30 33 41 44

Despite the shown significant dependence of survival from mEHT dose (p=0.007), it is difficult to say how the difference in the mEHT dose actually affects the response and survival because the LD-mEHT sample included weakened patients with longer time since diagnosis to first mEHT (median 9.9 months (95% CI 6.1 to 11.6)), shortest treatment time (median 0.5 months (95% CI 0.4 to 0.6) vs 1.9 months (95% CI 1.2 to 2.8) in the HD-mEHT sample, p=0.0001) and highest rate of treatment termination (38% vs 0% in the HD-mEHT sample, p<0.0001) (table 2). More correctly, the LD-mEHT was rather a sequence of poor patient states, which likely accounts for the decrease in survival. In other words, the impossibility to reach an adequate mEHT dose for weakened patients made their prognosis dismal.

The dependence of survival on SAT use is questioned. The extremely low survival in the ‘No SAT’ sample (2.9 months (95% CI 2.3 to 5.5), almost twofold lower than the expected value) undisputedly indicates for the selection of patients with bad prognosis and small life expectancy. Comparison of the samples showed that ‘No SAT’ includes patients with significantly less TMZ cycles (mean 1.1±0.1 cycles vs 1.7±0.1, p=0.017) and mEHT sessions (mean, 11.2±0.5; median, 10 vs 19.9±0.4; median, 15, p=0.013) with a higher proportion of LD-mEHT (47% vs 27%, RR=1.74 (0.90–3.34), p=0.12). Therefore, this survival difference shows a tendency to not apply SAT to patients with a bad prognosis, and that these patients were heavily undertreated.

The shown significantly reduced toxicity of ddTMZ+mEHT is, in our opinion, caused by the short course of TMZ in the COI (median one cycle only). TMZ is known as a relatively safe alkylating drug. Its toxicity appears after two to three cycles and a development of the grade III–IV lymphopoenia (the main adverse event) becomes virtually inevitable after six cycles. Thus, the data presented here allow us to conclude that mEHT per se is safe, but do not allow us to estimate the modifying effect of mEHT on TMZ toxicity (if such an effect exists).

Effect-to-treatment analysis

Direct comparison of the ddTMZ+mEHT results with the other ddTMZ studies is impossible because the ddTMZ+mEHT treatment in the participating tertiary centres was not continued up to the maximal attainable course (MAC). The median number of cycles was just one, and only 15% of treatments were stopped in view of the disease progression, without limiting toxicity. In tertiary centres, the end of treatment is caused either by the physician’s decision, by the patient’s personal decision, economic reasons, by an applied protocol or because of a combination of these reasons. Therefore, the treatment is typically limited by one to three cycles only, whereas in clinics the median duration of MAC of recurrent GBM is five cycles.18 Therefore, ETA was used for the comparison.143

The idea of ETA is simple and based on the ETR, that is, life months gained per a typical 28 days treatment cycle, which is considered a unit of a CTX treatment. By ETR, we identified ddTMZ+mEHT as the uncontested leader, with 1.83 LMG/ccl vs 1.13 LMG/ccl of the nearest competitor (cohort by Brandes et al) and 0.58 LMG/ccl of the main comparator (WA 2–4) (table 6), although in terms of conventional MST-based comparison, ddTMZ+mEHT was ranked third (behind the cohorts by Brandes et al and Strik et al).

The next step of the ETA follows from the idea of attenuation of the treatment effect. This is a typical feature of all cancer treatments because of the ability of cancer cells to rapidly develop multiple mechanisms of acquired resistance to an applied treatment. This is especially correct for diseases such as GBM, which almost inevitably progresses, and for TMZ, for which many distinct mechanisms of acquired resistance are available,160–162 so that virtually all patients develop resistance to TMZ. As a result, the effectiveness of any cancer treatment decays (attenuates).

The offered equation of the attenuation is based on ETR and CA. It is suggested that CA is common for all the ddTMZ cohorts. The maximum value of CA corresponds to the assumption that the treatments have almost reached MAST, which equals the extremum of the function. In this case, CA=15%/ccl exactly matches this assumption (table 7A). Although the cohort by Strik et al is located after the maximum of the function, it is acceptable because this cohort is likely overtreated (mNC=7.3 ccls vs 3–4.5 ccls in other ddTMZ cohorts).

The natural sequence of the attenuation idea is incomparability of ETRs obtained in a different number of cycles. This is because an early ETR with the lower impact of attenuation is higher than a later one. For the correct comparison, ETRs should be led to the common denominator. The best common denominator is the MNC, which equals 4.2 cycles. The resulting parameter METR allows us to correctly compare the different treatments. In this comparison, COI (METR=1.19 LMG/ccl (95% CI 0.59 to 2.40)) significantly surpasses the main comparator WA (2–4) (METR=0.57 LMG/ccl (95% CI 0.39 to 0.85), p=0.011) and all other comparators (METR=0.19–0.59, p=0.00–0.016), except the cohorts by Brandes et al (METR=1.20 LMG/ccl (0.74–1.95), p=0.979) and Strik et al (METR=0.81 LMG/ccl (0.44–1.48), p=0.302) (table 7). In other words, the efficacy of IOI in CTX-pretreated patients with a median KPS of 60%–70% is the same as in the selected cohort of CTX-naïve patients with a median KPS of 90%, and significantly better compared with the TMZ-pretreated cohorts.

With CA 15%/ccl, the COI reach a MAST of 10.10 months (95% CI 9.10 to 11.10) at the sixth cycle, which is significantly more than the MAST of the main comparator (7.34 months (95% CI 6.46 to 8.21), p<0.001) and other cohorts, except the cohort by Brandes et al (10.15 months (95% CI 9.24 to 11.06), p=0.943). The next assumption is that the CA of the ddTMZ+mEHT regimen is lower than that of the ddTMZ-only regimen. Actually, the mechanisms of resistance to the RF field have to differ substantially from those of CTX. Little is known about such acquired resistance. TTF reports a possibility of selection or development of giant-cell GBM with syncytial-type cells,163 which is reasonable adaptation for 100 kHz range, where the large size of a cell improves the shielding from the external field, although it is a single-case observation, and it is hardly applicable to high-frequency range (HFR), where size difference is not decisive. Taking into account the results of long-term (6 months to 3 years) mEHT treatments,33 45 47 especially in patients with multiple liver metastases, which is a similarly lethal condition as GBM, where mEHT displayed the ability to support PFS up to 3 years, and even to revert the progression after stopping mEHT33 (ie, mEHT does not lose its efficacy over years), the assumption that the CA of mEHT is lower than that of TMZ looks reasonable. If we assume that the CA=12.5%/ccl, the ddTMX+mEHT cohort can attain a MAST of 10.84 months, or of 12.13 months with a CA=10.0%.

The last parameter of ETA, called ‘cycles needed to treat per one life month gained’ (CNTM), is an analogue of the known parameter ‘number needed to treat’ (NNT). The CNTM shows the number of cycles of the compared treatments, at which the difference in their MST reaches 1 month. Positive CNTM means a benefit, negative means detriment, and the value of CNTM characterises the strength of the effect (figure 9). In this comparison, all of the cohorts displayed strong to moderate detriment versus the ddTMZ+mEHT regimen (table 7), except the cohort by Brandes et al (no effect).

Figure 9

Cycles needed to treat per one life-month gained (CNTM) scale.

Thus, the ETA has allowed us to uncover the real efficacy of the ddTMZ+mEHT treatment, which was impossible to assess with the conventional comparison by general end points, and has suggested that mEHT strongly and significantly enhances the efficacy of the ddTMZ 21/28 d regimen with significantly less toxicity.

Economic evaluation

We studied two options for the mEHT application. The first, so-called German option, is specific for a high-income country with rigid governmental regulation of the medical market, which leads to relatively low prices for pharmaceuticals with low variance (mean price of TMZ is €1.14/mg (95% CI 1.12 to 1.17)) and fixed and low enough prices for medical procedures (in this case, €145.14/sess with zero variance (95% CI 145.14 to 145.14)). The second, so-called US option, is specific for a high-income country with lower governmental regulation, which leads to relatively high prices for pharmaceuticals with higher variance (mean price of TMZ US$1.70/mg (95% CI 1.44 to 1.95)) and variable and high enough prices for medical procedures (in this case, US$300/sess (95% CI 234 to 366)).

First, the adequacy of our costs estimation (€18 138 (95% CI, 17 750 to 18 527)) and US$26 901 (95% CI 22 877 to 30 925) in the main comparator) have to be assessed (tables 11 and 12). For this purpose, the result was compared with a recent study by Ray et al,19 where expenditures for cancer drugs (without supportive drugs like antiemetics, pain killers, neutropaenia related, etc) for a 6-month period were assessed as US$13 555–US$17 204. Since the study was devoted to TMZ treatment and taking into account the difference in price of TMZ and other cancer drugs, 95%–99% of these ‘cancer drugs’ costs can be attributed to TMZ. Although the reported range of US$13 555–US$17 204 appears to be much less than the average US$27 000 displayed in the current assessment, it should be noted that the general practice of recurrent GBM treatment is based almost exclusively on the standard TMZ 5/28 d regimen9, with 100–150 mg/m2/day. The current regimen ddTMZ 21/28 d 75–100 mg/m2/day consumes 2.1–4.2 times more TMZ per course. Therefore, it is at least two to three times more expensive. Thus, the estimated costs range for the ddTMZ 21/28 d regimen is US$27 000–US$50 000, and the cost estimation of the current trial is adequate. It also corresponds to other estimations.17 18

The result suggests the significant advantage of the ddTMZ+mEHT regimen over all the comparators (p<0.003) (except the cohort by Brandes et al, against which the advantage was not significant (p=0.061–0.472)). In the German model (table 11), the ddTMZ+mEHT regimen was cost-effective versus both the €25 000/QALY and €30 000/QALY cost-effectiveness thresholds (CET) (88.8% and 99.2% of cost-effective cases, respectively), whereas the main comparator was not cost-effective (%CE of 0.0% and 0.2%). ICER versus ddTMZ+mEHT varied from €43 717/QALY to €367 368/QALY (except for the cohort by Brandes et al, which displayed an ICER of €28 706/QALY).

In the US model (table 12), the pattern was the same with more pronounced differences. The ddTMZ+mEHT regimen was not cost-effective versus CET=US$30 000/QALY (%CE=4.5% only), and only CET US$50 000 /QALY provides cost-effectiveness (%CE=94.6%), whereas the main comparator showed a negligible cost-effectiveness (%CE50k = 2.0%). ICER versus ddTMZ+mEHT varied from US$55 827/QALY to US$519 683/QALY (except for the cohort by Brandes et al, which displayed an ICER of US$34 727/QALY).

The CET (or willingness-to-pay (WTP)) is set by the National Institute for Health and Care Excellence (NICE) at £20 000–£30 000/QALY,164 although studies show that the acceptable limit can be lower (up to £13–£14 000).165 In high-income countries, a CET of €/US$/£30 000 is considered standard. The CET for low-income and middle-income countries is suggested by WHO at the level of their triple GDP per capita for each disability-adjusted life-year,166 which is typically close to the above NICE WTP. For end-of-life applications, where the QALY increase could be negligible, a CET of £50 000 is supposed by NICE.167 Finally, for some orphan diseases, the third CET of about £100 000 is offered.168 Since a treatment of the recurrent GBM can be considered an end-of-life application, a CET of US$50 000/QALY is applicable in the US model.

Thus, the economic evaluation suggests that the inclusion of mEHT in the ddTMZ 21/28 d regimen makes it cost-effective versus the applicable CET levels, whereas the ddTMZ 21/28 d alone is not cost-effective. The sensitivity analysis suggests that this estimation is highly reliable, with double to quadruple redundancy. The sensitivity analysis also suggests that the advantage of ddTMZ+mEHT in cost-effectiveness remains true throughout the entire applicable range of prices for TMZ and the mEHT procedure, as well as for the TMZ intercycle variances (ie, up to the lowest 5/28 d regimen). It also suggests that the ddTMZ+mEHT course can be at least doubled without loss of cost-effectiveness. Since the CENC (ie, the number of cycles at which MST reaches 95% of MAST) for the ddTMZ+mEHT regimen equals 3.0 (table 7), this means the all-range cost-effectiveness of the regimen.

The BIA suggests significant savings from the introduction of mEHT, which can be estimated as about €8 794 882 per year per 1000 patients in the German model and US$11 523 498 per year per 1000 patients in the US model, with an additional 29.1–38.5 QALY gained per 1000 patients.

Finally, the CBA shows that the mEHT, from the perspective of a single neurooncology centre, is profitable in both of the tested models (tables 14 and 15).

Thus, the introduction of mEHT generates savings for budget and healthcare providers and significant profit for the latter.

Applicability of mEHT in GBM treatment

The result obtained in this study looks promising, although a single retrospective trial does not provide the necessary grounds for generalisation. Nevertheless, if the result is confirmed in a further meta-analysis, it will provide an excellent ground for generalisation. At the least, it means that mEHT can be recommended as an enhancer of all ddTMZ regimens in the treatment of recurrent GBM, and, probably, for the regular 5/28 d regimen too. Next, as shown by the covariates survival analysis (figure 5), mEHT is feasible as a single treatment in those patients for which chemotherapy is impossible because of toxicity or bad performance. Thus, mEHT has a capacity as a salvage treatment after the failure of chemotherapy. With respect to the known low toxicity of mEHT22–26 and its possibility to restore the performance and chemosensitivity,33 45 47 this salvage treatment can, in some cases, provide an opportunity to continue chemotherapy in previously failed patients.

Bias assessment and limitations of the study

Only 15 patients (28%) in the COI were assessed for response. Although natural selection is supposed, selection bias is not excluded. Consequently, the response rate was excluded from the analysis.

Although follow-up period was short enough (median 6.0 months; range 0.7–47.3 months; 95% CI 4.6 to 7.5 months), it is close to the MST since the first mEHT session (7.7 months, 95% CI 5.7 to 9.4), and the mean of the follow-up (8.4±1.2 months) exactly fits the CI of the MST. Thus, the MST value is robust. Although 1-year and 2-year survivals since first mEHT are less robust in view of the short follow-up, they are also well within the range of the follow-up time (0.7–47.3 months) and, therefore, are reliable enough. Nevertheless, in view of their lower reliability, the 1-year and 2-year survivals were excluded from the comparison, which was based solely on the robust MST value.

The absence of the safety data matched to the COI is not a serious limitation because the absence of severe toxicity in the whole sample also excludes it for the subsamples. So, the absence of grade III–IV toxicity and limited grade I–II toxicity (up to 30%) findings are relevant and robust, although the rate and distribution of the mild toxicity in the COI are approximate.

We excluded the trial by Norden et al 154 from the ETA because of a lack of information on the number of cycles and some uncertainties (eg, survival definition and some statistical uncertainties). The modest effect shown would not affect the comparison.

The main possible bias of a retrospective study is a selection bias. We consider the probability of the selection bias as minimal in the SOI because, in addition to the assurances of the authors of no exclusions from the sample, 153 patients with HGG is consistent with such patients in the enrolling centres, which are small tertiary centres not specialised in neurooncology (and, in the case of the Institute of Microtherapy, in cancer care at all), for the 5-year period. Thus, we consider the sample as consecutive patients with HGG enrolled for the stated period without exclusions or selection. The declared inclusion criteria (recurrence/progression of HGG with KPS ≥40%) rather describe the sample than limit it in any way. The absence of exclusion criteria confirms this suggestion.

At the same time, some compared ddTMZ studies showed an obvious selection bias. First, the study by Brandes et al, in which the selection of CTX-naïve patients is presumed by the protocol, but the selection of patients with good performance (median KPS=90%) also seems to be present (although this might be a natural sequence of the inclusion criteria). The same extremely favourable KPS is shown in the excluded trial by Norden et al, which also showed an extremely high share of MGMT methylated patients (65% vs 45%–46% in the other trials, which exceeds the highest historical level of about 60%13 (table 6). Also, the large share of re-operations in the study by Strik et al (33.3%) might significantly improve the observed survival, making it hardly attributable to the applied ddTMZ treatment.

The difference in dosage between the ddTMZ regimens was not analysed in the ETA (although it was considered in the economic evaluation). As many studies had displayed, there is no or negligible difference in efficacy of different doses of ddTMZ regimens, and sometimes lower doses were preferable.169 Moreover, the possibility of dose reduction/escalation in all of the protocols makes such an analysis impossible. The average dose is never reported and cannot be retrieved from the reported data. We do not exclude the possibility that the actual doses were similar to each other.

There is an unequal MST starting point bias because the MST in the ddTMZ+mEHT cohort was calculated since the first session of mEHT, rather than since relapse/progression in the other cohorts. Since the SOI was carried out in tertiary centres, it is normal that mEHT was applied not just after relapse but rather as the second-line treatment of the relapse. Based on the median time of 9.0 months elapsed since diagnosis to the first mEHT treatment, and estimated 7.5 months MPFS in GBM, the delay of mEHT since relapse can be 1–1.5 months. This could significantly change the results in favour of the ddTMZ+mEHT cohort (eg, estimated MST since relapse can reach 9 months instead of 7.6 months, as in the best ddTMZ studies). At the same time, due to this delay, probably some first-line treatments of relapse in the SOI were not included in the assessment. Based on the delay, the median one treatment cycle is supposed to be added, increasing the mean CTX cycles number to 2–2.5, which can somewhat change the economic results in favour of concurrent ddTMZ studies. Thus, the bias of not equal MST starting point rather distorts the comparison in favour of ddTMZ studies, although economically it is somewhat counterbalanced.

It should also be noted that the two ‘real-life’ studies by Abacioglu et al and Berrocal et al displayed the longest time from initial diagnosis to enrolment (13 and 14 months, respectively), which is responsible for the low MST values in these trials. We consider that, in the weighted average assessment, this difference is counterbalanced by early enrolment in the trials by Brandes et al and Strik et al and the median position of the SOI (table 7). It is also counterbalanced (and even outbalanced) by the unequal histology bias, since the trials by Abacioglu et al and Berrocal et al included WHO III tumours (28% and 43%, respectively) with much longer survival, which can be, in turn, the reason for the delayed relapse.

Nevertheless, there is a reciprocal dependence between the time to enrolment (relapse) and the MST since the enrolment (the SOI displays the medium-power correlation, Pearson’s correlation 0.35), which is not considered in the ETA but seems counterbalanced or even outbalanced in favour of the ddTMZ cohorts.

It is worth noting that all of the ‘real-life’ studies (ie, studies by Sahinbas et al, Berrocal et al and Abaciouglu et al) showed the same median age of 50 years, whereas the supposedly selection-biased trials included the older patients (55–57 years).

MEHT required additional visits to the hospital (two to three times a week), which means additional transportation costs and influences cost-effectiveness from the patient’s perspective, although this does not affect the assessment from the health provider perspective. At the same time, since a planned mEHT session typically does not require the physician’s involvement (a nursing procedure), we do not assume a better treatment control. Moreover, such control seems much more extensive in the compared prospective trials, where the follow-up included weekly complete blood counts,154 155 physical and neurological examinations every 4 weeks,153 155 or even biweekly155 and brain imaging with MRI every 8 weeks154 or earlier if indicated.153 To compare, only 28% of patients in the SOI underwent brain imaging (the specificity of small tertiary centres). Better treatment control could significantly improve the treatment results.

Finally, all of the compared ddTMZ studies recruited only patients in a stable condition, whereas there was no such limitation in the SOI.

In general, although the assessment is distorted in favour of the ddTMZ studies, it still allows us to make an unambiguous conclusion on the advantage of the combination of mEHT and TMZ.

Also, on completion of the paper, we have identified one additional ddTMZ 21/28 d cohort in phase III randomised trial of Brada et al.169 The result of this cohort (MST since relapse 6.6 months after median four ddTMZ cycles, which results in METR ≤0.5 LMG/ccl) would not in any way affect the results obtained.

Generalisability of the results

The results of the sensitivity analysis of the CEA supposes the generalisability of the CEA results to the entire range of application of TMZ at recurrent GBM. There is a probability of similar enhancement of TMZ efficacy and cost-efficiency by mEHT can also be achieved in the treatment of the newly diagnosed GBM, although, to the best our knowledge, mEHT has never been studied in such a setting.

Since TMZ is considered the current most effective CTX treatment of GBM, the results of the covariate survival analysis (figure 4) can be generalised to CTX. Thus, mEHT as a single treatment can be considered in those patients for which CTX is impossible because of toxicity or bad performance, and mEHT has a capacity as a salvage treatment after the failure of CTX.

Perspectives of research

This study creates a good basis for the further research on mEHT enhancement of the GBM treatments with the possibility to develop a cost-effective alternative. First, we will estimate the other existing mEHT cohort trials, followed by a systematic review with meta-analysis. Second, a new cohort and randomised trials at recurrent and newly diagnosed GBM are warranted.

Verifiability of the results

To provide the possibility to verify the results obtained, raw data of the study are available in online supplementary 3.

Supplementary Material

Supplementary data


Our ETA suggests that mEHT strongly and significantly enhances the efficacy of the ddTMZ 21/28 d regimen (p=0.011), with a maximum attainable MST of 10.10 months (95% CI 9.10 to 11.10). The ddTMZ+mEHT cohort has displayed significantly less toxicity than the ddTMZ 21/28 d cohorts (no grade III–IV toxicity vs 45%–92%, respectively) because of the shorter TMZ course. mEHT per se displays high safety with a mild grade I–II toxicity (30% of events), mainly of mild skin reactions (12%) and short (<2 hours) post-treatment asthenia (10%). Our CEA suggests that the ddTMZ+mEHT regimen is cost-effective compared with the applicable cost-effectiveness thresholds €$25 000–50 000/QALY, whereas ddTMZ 21/28 d only is not cost-effective, with ICER versus ddTMZ+mEHT ranging from €43 717/QALY to €367 368/QALY. This CEA result is highly reliable with double to quadruple redundancy. Our BIA suggests a significant saving from the introduction of mEHT, which can be estimated from €8 577 947 to $11 523 498 with 29.1–38.5 QALY gained per 1000 patients. The CBA, from the perspective of a single neurooncology centre, suggests that mEHT is profitable and will generate a total revenue of €3 124 574–$6 458 400 with total economic effect (economy +EBIT) of €5 700 034–$8 237 432 per mEHT device over an 8-year period. After confirmation of these findings, mEHT can be recommended as an enhancer for all ddTMZ regimens in the treatment of recurrent GBM, and, probably, for the regular 5/28 d regimen. mEHT can be applied as a single treatment in those patients for which chemotherapy is impossible because of its toxicity or bad performance, and as a salvage treatment after the failure of chemotherapy, with a possibility to restore the patient’s performance and chemosensitivity and subsequently continue chemotherapy.

Supplementary Material

Supplementary data


The authors would like to thank Professor Andras Szasz from Szent István University (Godollo, Hungary), who provided the primary data for the study. The authors would like to thank all the other authors of the original study,23 namely Dr Hüseyin Sahinbas and Professor Dietrich HW Grönemeyer from the Institute of Microtherapy of University Witten-Herdecke (Bochum, Germany) and Dr Eckhard Böcher from Clinic ‘Closter Paradise’ (Soest, Germany) for conducting this remarkable trial, although they may not agree with all the interpretations and conclusions of this paper. The authors would also like to thank for proofreading of the paper.


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  • Contributors SVR is the only contributor and guarantor, solely responsible for its writing and contents. No other persons or professional writers are involved.

  • Competing interests None declared.

  • Provenance and peer review Not commissioned; externally peer reviewed.

  • Data sharing statement Patient level data are available in the online supplementary 3. Consent for data sharing was not obtained but the presented data are completely anonymised, and risk of identification is absent.