Abstract
Background
Iodine-123-metaiodobenzylguanidine (123I-MIBG) imaging with estimation of the heart-to-mediastinum ratio (HMR) has been established for risk assessment in patients with chronic heart failure. Our aim was to evaluate the effect of different methods of ROI definition on the renderability of HMR to normal or decreased sympathetic innervation.
Methods and Results
The results of three different methods of ROI definition (clinical routine (CLI), simple standardization (STA), and semi-automated (AUT) were compared. Ranges of 95% limits of agreement (LoA) of inter-observer variabilities were 0.28 and 0.13 for STA and AUT, respectively. Considering a HMR of 1.60 as the lower limit of normal, 13 of 32 (41%) for method STA and 5 of 32 (16%) for method AUT of all HMR measurements could not be classified to normal or pathologic. Ranges of 95% LoA of inter-method variabilities were 0.72 for CLI vs AUT, 0.65 for CLI vs STA, and 0.31 for STA vs AUT.
Conclusion
Different methods of ROI definition result in different ranges of the LoA of the measured HMR with relevance for rendering the results to normal or pathological innervation. We could demonstrate that standardized protocols can help keep methodological variabilities limited, narrowing the gray zone of renderability.
Similar content being viewed by others
Explore related subjects
Discover the latest articles, news and stories from top researchers in related subjects.Avoid common mistakes on your manuscript.
Introduction
Since the first clinical reports more than 35 years ago, 123I-MIBG imaging developed to a widely accepted tool in the diagnostics of disorders of sympathetic cardiac innervation.1-3 In clinical context, 123I-MIBG is mainly used in patients with documented chronic heart failure and decreased left ventricular ejection fraction in order to identify patients with increased short-term risk of cardiac mortality.4-7
As the determination of absolute myocardial uptake of 123I-MIBG is not feasible at present, the use of the heart-to-mediastinum ratio (HMR) was introduced and validated for the characterization of global myocardial sympathetic innervation.8-10 Based on the results of a large prospective multicenter clinical trial, a HMR cut-off of 1.6 is now generally used for the identification of patients with high mortality risk.4
General limitations of such translating a cut-off value of the continuous variable HMR into the categories high and low mortality risk have recently been discussed elsewhere.11 From technical point of view, the selection of collimator and implementation of scatter correction as well as the introduction of quantitative SPECT imaging may influence HMR systematically and, therefore, may lead to different cut-off values.12-14
A further, potentially relevant technical factor, which may have influence on the value and the variability of HMR, is the method of ROI definition.15-17 In this context, most publications reported generally good observer reproducibility.15,17-19 However, even relatively small variability values may be clinically relevant, and this issue has rather been underestimated in the past.11,20
Additionally, in everyday clinical practice, ROI setting is performed by different certified nuclear medicine technicians and is not completely standardized.
The aim of our study was to compare the inter-observer and intra-observer variabilities of a minimally standardized manual method of ROI definition with a semi-automated tool published earlier.21 Furthermore, we tested the comparability of HMR obtained by one of the methods described above with those generated in the clinical routine diagnostics.
Material and Methods
We retrospectively analyzed 32 digitally archived planar images of 20 consecutive patients (median 63.5 years; 2 females, 18 males) who were referred to 123I-MIBG imaging between January 2014 and October 2015. 60% of these patients (12/20) had cardiac arrhythmias, and in 40% (8/20), neurodegenerative disease was suspected. The patients had a mean heart rate of 74 ± 20/min (range 50-134/min) and a mean blood pressure of 124/75 ± 14/12 mmHg (range 95/50-150/90 mmHg). Among the patients, 40% (8/20) suffered from hypertension, 20% (4/20) from diabetes, and 35% (7/20) from dyslipidemia, respectively. Regarding the patients with cardiac arrhythmias, 16.7% (2/12) had an implantable cardioverter defibrillator (ICD), 25% (3/12) were treated with ventricular tachycardia (VT) ablation, and 83.3% (10/12) were treated with pulmonary vein isolation (PVI). Furthermore, 100% (12/12) received beta blockers and 58.3% (7/12) antihypertensive medication, respectively. Among the patients with suspected neurodegenerative disease, 87.5% (7/8) received antiparkinson medication. All patients gave written informed consent. The retrospective evaluation was approved by the local Ethics Committee (No.: WF-056/15).
123I-MIBG Imaging Protocol
Patients underwent planar imaging at 15 minutes and 4 hours (n = 12) or only at 4 hours (n = 8) after injection of 185 MBq (n = 10) or 370 MBq (n = 10) 123I-MIBG (AdreView™, GE Healthcare B.V., Eindhoven, The Netherlands). Images were acquired with the anterior view over the thoracic region. The acquisition time was 10 minutes (zoom 1.0, matrix 256 × 256, pixel size 2.4 × 2.4 mm). We used ECAM variable angle or Symbia T (Siemens Medical Solutions, Hoffman Estates, USA) gamma camera system with standard LEHR collimators of the manufacturer.
Image Processing
Three different methods for ROI definition were used to determine HMR (Figure 1):
-
Method CLI: Heart and mediastinal ROIs were defined manually in daily clinical routine by experienced nuclear medicine technologists, who did not receive further specific instructions.
-
Method STA: The cardiac ROI was manually set by carefully considering the outline of the myocardium and the plane of the left ventricles’ base. A circular mediastinal ROI was drawn in the upper mediastinum around the point with visually lowest regional activity with a size of at least 4 cm2. This procedure was performed by an experienced staff member of the University Hospital Hamburg-Eppendorf (JM) and repeated three weeks after the first evaluation (intra-observer variability). A third evaluation was performed by a second member of staff (CK) with about nine months of clinical experience (inter-observer variability).
-
Method AUT: ROIs were defined using a dedicated semi-automated software as described previously21 by two staff members of the Kanazawa University (KN) and Kanazawa Medical University (KO). Briefly, after pointing into the center of the heart, circular ROI was automatically determined on the heart, for which the radius can be manually changed, if required. A rectangular ROI was automatically placed in the upper mediastinum with a 10% width of the body and a 30% height from the center of the heart to the upper border of the mediastinum. Even with manual adjustment, an operator cannot move the mediastinal ROI directly but adjust only the range of the chest including right and left borders, upper limit of the mediastinum, and the center of the heart. The evaluation was then repeated after 3 weeks (KN) (intra- and inter-observer variability).
Statistical Analysis
Concordance between methods or repeated evaluations was investigated by Bland-Altman-analysis.22 95% limits of agreement (LoA) were expressed as mean of the differences ± 1.96 standard deviation (SD).
Inter-method variability was determined by direct comparison of two methods for all combinations of the methods CLI, STA, and AUT. For the methods STA and AUT, the first observed HMRs, which were used to determine their intra-observer variability, were used.23
Furthermore, the inter-method variability of the methods STA and AUT was assessed by the formula reported by Bland and Altman22,24
where SDIMV,BC is the total inter-method variability between STA and AUT, SDBC is the inter-method variability determined by direct comparison of the first observed HMRs of the methods STA and AUT, SDB, intra is the intra-observer variability of method STA, and SDC, intra is the intra-observer variability of method AUT.
Single-factor variance analyses were performed to assess statistical significances of differences between the methods using the analysis of variance (ANOVA) and the post-hoc Tukey-Test.
We also calculated the washout rates (WRs) for 12 patients who underwent early and late imaging using the formula.10
where \( H \) and \( M \) are the mean counts per pixel of the ROI placed over the left ventricle and the upper mediastinum, respectively. The indices e and l refer to early images and late images, respectively. \( k \) is the decay correction factor, assuming that half life of 123I is 13 hours.
All statistic evaluations were performed using SPSS (Version 23.0. IBM Corp. Armonk NY, USA). Data were expressed as mean ± SD. Mean values of differences of HMR were tested using Student’s t test for paired samples. P ≤ 0.05 was considered statistically significant. In order to avoid overestimation of variability, outliers due to definitive ROI displacement during routine data processing were identified and eliminated.
Results
Outliers
Analysis of Bland-Altman-plots revealed three outliers. In one case, we could identify an obvious misplacement of the cardiac ROI with overestimation of the heart extension which included parts of the lung in this region. Consequently, we excluded this result from further analysis. In the other two outliers, no obvious ROI misplacement was identified, and so these data were used for further analysis (Figure 2).
Comparison of Different Methods of ROI Definition
Pairwise comparison of HMR obtained with different methods of ROI definition is depicted (Table 1), and corresponding Bland-Altman plots are presented in Figure 2. The results for the mean difference from comparing the methods CLI with STA, CLI with AUT, and STA were −0.14, −0.22 and −0.08, respectively. SD of the difference resulting from comparing method STA with AUT was 0.09, CLI with STA 0.17, and 0.19 for comparing method CLI with AUT. Including the results of the single-factor variance analyses, ANOVA revealed a significance for comparison among the three methods (P = 0.01). The outcome of the post-hoc Tukey-test confirmed the aforementioned results: Comparing method CLI with AUT, there was a significant difference (P = 0.01) (Table 1). The comparisons between method CLI with STA (P = 0.13) and between method STA with AUT (P = 0.45) demonstrated no significant differences.
Intra- and Inter-observer Variability
Table 2 summarizes the estimated inter- and intra-observer variability for STA and AUT, including the respective 95% LoA and the corresponding numbers of HMRs belonging to the gray zone around 1.60, which was considered the lower limit of normal sympathetic innervation.
The intra-observer variabilities for both methods were 0.01 ± 0.05 (mean difference ± SD), the 95% LoA for STA were −0.09-0.11, and for AUT -0.08-0.10.
Considering the inter-observer variability, the values were −0.07 ± 0.07 for method STA and 0.01 ± 0.03 for method AUT. The 95% LoA for method STA was −0.21-0.07 and for method AUT −0.06-0.07 (Table 2). Method AUT presented the smaller inter-observer variability and seemed to be the most stable method.
Defining the 95% LoA as the width of the gray zone and transferring it to the HMR value of 1.60 as the normal limit according to the ADMIRE-HF study, the corresponding limits were 1.46-1.74 for method STA and 1.54-1.66 for method AUT, respectively (Figure 3). Thus, of all HMR measurements in our study, 13 of 32 (41%) for method STA, and 5 of 32 (16%) for method AUT, respectively, were lying within this gray zone and could not be rendered to normal or pathologic sympathetic cardiac innervation.
Washout Rate
Table 3 shows the results for the calculated WRs in 12 patients for methods CLI, STA, and AUT. Concerning the difference between two methods, the SDs of WRs are 7.9% for method CLI and STA, 5.8% for method CLI and AUT, and 3.6% for method STA and AUT. The SDs of the WRs concerning the difference between two observers within one method are 5.3% for method STA and 2.6% for method AUT.
Discussion
123I-MIBG scintigraphy is a worldwide established method for the evaluation of sympathetic neuronal innervation of the myocardium. It is relevant in evaluation of the prognostic risk of sudden cardiac death in patients with cardiomyopathies and chronic heart failure. Different quantification methods are used in daily clinical routine to determine the HMR, which classifies patients into different risk groups. As a result of the international multicenter ADMIRE-HF study,4 the cut-off value defining patients at risk for fatal arrhythmias has been set at a value of 1.60.
Methodological Considerations
Several factors influence the HMR. Apart from the time points of data acquisition and the specific activity of 123I-MIBG, parameters of data acquisition including selection of collimator and especially ROI definition are critical factors. Surprisingly, the guidelines for 123I-MIBG in cardiac diagnosis10 do not give explicit advice about ROI definition. Somsen et al. indicate the influence of the shape of myocardial ROIs and recommend the use of a standardized shape of the myocardial ROI, including the myocardium and the left ventricular cavity.16,17 Some studies consider the size of mediastinal ROI, but do neither give general recommendations for exact ROI placement nor discuss the effect of ROI positioning on HMR values.17 However, it has been demonstrated that the HMR is in general highly reproducible by analyzing intra- and inter-observer variabilities.15 This was supported by a recent study, stating that the size of manually set ROI in the visually best position does not have a clinically relevant effect on the HMR.19 Other studies confirmed the good agreement in intra- and inter-observer variability using only manual analysis.19 Using a semi-automated ROI definition also leads to low intra-observer variability (less than 0.1) as described by Okuda et al.21 In line with this study, we found a low intra- and also a low inter-observer variability during semi-automated HMR analysis (Method AUT).
Interestingly, only minimal standardization in manual ROI definition (Method STA), by recommending to set the mediastinal ROI around the area with minimal regional activity, resulted in variable values similar to the semiautomatic method (Method AUT). However, we also demonstrated that comparing standardized or semi-automated analysis methods (Method STA and AUT) with a non-standardized method (Method CLI) leads to a significantly higher variability. Table 4 gives a literature overview of different HMR analysis methods and the respective inter- and intra-observer variabilities.
Due to the limited number of patients, data of WR are to be interpreted carefully. Comparing the results of HMR and WR, the tendencies are the same: method CLI has the highest variability, and method AUT has the lowest.
As WR is calculated based on the ROIs for heart and mediastinum, standardization might therefore have a stabilizing effect.
The Gray Zone and Its Consequences for Patient Classification
A major challenge in HMR analysis is to determine a cut-off value using a continuous variable for dichotomizing a binary decision resulting in a relevant gray zone.11
Transferring the uncertainty of HMR analysis to our patient data reveals that using a confidence interval (CI) of 95% leaves even using a standardized evaluation protocol up to 40% of values in the measurement gray zone. HMR values close to the cut-off value make patient classification challenging. Further, when only one HMR measurement falls between 1.50 and 1.60, there is a relevant chance that the classification will change if the measurement is repeated. A practical question from these data is how confident is the assignment of the individual patient to each of the risk categories,20 and how reliable 123I-MIBG studies are.
Reproducibility of HMR is especially relevant when repeated measurements are necessary to evaluate disease progress or changes after interventions.25 Some studies found that HMR on 123I-MIBG imaging provides prognostic information in patients with chronic heart failure26,27 and dilated cardiomyopathy,28 although neither of them assessed the reproducibility of 123I-MIBG imaging.
Otherwise, some authors found a high reproducibility of planar HMRs18 and SPECT defect scores in heart failure patients.15 Our analysis reveals that HMR results can vary from measurement to measurement and should not be taken as strict values to determine the patients’ prognosis or treatment, especially close to the cut-off value. This problem can be compensated at least partly by estimating probability of cardiac events considering HMR merely as a parameter among others for individual risk estimation. This assessment is supported by a study from Nakajima et al.29 predicting, model-based, different 5-year mortalities for patients with chronic heart failure.
Regarding the role of WR, no specific WR has been determined as the optimal threshold. In literature of 123I-MIBG for prognostic evaluation, threshold for discriminating good and poor prognosis ranged from 27% to 67%, and a normal 123I-MIBG database in Japan showed the upper limit of 34%.30 Our study, however, showed that potential variation of approximately ±10% could happen depending on the ROI setting. If the 20% range is a tentative gray zone for WR, 30%-40% data points in our study could be included in this range. Since the standardized or automatic methods reduced variability of WR, ROI setting should also be standardized for steady WR calculation.
Considering that intra- and inter-observer variabilities are either not taken into account or vary from study to study (Table 2), it may be of relevance to generate an internal measurement gray zone. To facilitate this process, anonymized data exchange between clinics could support this database.
Limitations
Concerning method CLI, HMRs were determined only once in order to avoid stabilizing effects of repeated evaluations.32 Consequently, the intra- as well as the inter-observer variability could not be determined for this method. The corresponding variability and its effect on the gray zone could therefore only be discussed indirectly.
Due to the limited number of patients, results of WR have mainly exemplary character and do not allow final conclusions. However, the influence of ROI setting on WR was demonstrated as crucial. A further possible limitation is the lacking of clinical gold standard partly due to inclusion of cardiology and neurology patients. Without using a gold standard, we could only demonstrate that the width of limits of methodical uncertainty depends on the evaluation method and might be of clinical relevance. Using a validated endpoint could support the discussion.
New Knowledge Gained
The effect of ROI definition on the HMR in cardiac sympathetic imaging has been rather underestimated in the past. We could demonstrate that in clinical context, depending on the method of ROI definition, up to about 40% of results may be lying in a gray zone around 1.6, where the rendering to normal or abnormal innervation is not possible. This problem may compensate using standardized evaluation methods, and their validation by means of clinical software phantoms is strongly recommended.
Conclusion
In 123I-MIBG imaging analysis, calculation of HMR is crucial for risk classification of patients with chronic heart failure. The lack of exact and standardized measurements leads to a variable gray zone influencing clinical decision making. In order to keep the consequences of methodological variabilities controlled, standardization and subsequent validation of analysis are essential. An internal validation of evaluation methods using anonymized datasets is strongly recommended.
Abbreviations
- ANOVA:
-
Analysis of variance
- AUT:
-
Evaluation with semi-automated software
- CI:
-
Confidence interval
- CLI:
-
Manual evaluation in daily clinical routine
- HMR:
-
Heart-to-mediastinum activity ratio
- 123I-MIBG:
-
Iodine-123-metaiodobenzylguanidine
- LoA:
-
Limits of agreement
- ROI:
-
Region of interest
- SD:
-
Standard deviation
- STA:
-
Manual standardized evaluation
- WR:
-
Washout rate
References
Wieland DM, Brown LE, Rogers W, Worthington KC, Wu J, Clinthorne NH, et al. Myocardial imaging with a radioiodinated norepinephrine storage analog. J Nucl Med 1981;22:22-31.
Soman P, Travin MI, Gerson M, Cullom SJ, Thompson R. I-123 MIBG cardiac imaging. J Nucl Cardiol 2015;22:677-85.
Nakajima K, Nakata T. Cardiac I-123-MIBG Imaging for clinical decision making: 22-year experience in Japan. J Nucl Med 2015;56:11S-9S.
Jacobson AF, Senior R, Cerqueira MD, Wong ND, Thomas GS, Lopez VA, et al. Myocardial iodine-123 meta-iodobenzylguanidine imaging and cardiac events in heart failure: Results of the prospective ADMIRE-HF (AdreView Myocardial Imaging for Risk Evaluation in Heart Failure) Study. JACC 2010;55:2212-21.
Nakajima K, Nakata T, Matsuo S, Jacobson AF. Creation of mortality risk charts using 123I meta-iodobenzylguanidine heart-to-mediastinum ratio in patients with heart failure: 2- and 5-year risk models. Eur Heart J Cardiovasc Imaging 2016; (Advance Pub 2015/12/24).
Travin MI. Cardiac radionuclide imaging to assess patients with heart failure. Semin Nucl Med 2014;44:294-313.
Peix A, Mesquita CT, Paez D, Pereira CC, Felix R, Gutierrez C, et al. Nuclear medicine in the management of patients with heart failure: guidance from an expert panel of the International Atomic Energy Agency (IAEA). Nucl Med Commun 2014;35:818-23.
Merlet P, Valette H, Duboisrande JL, Moyse D, Duboc D, Dove P, et al. Prognostic value of MIBG imaging in idiopathic dilated cardiomyopathy. J Nucl Med 1992;33:471-7.
Agostini D, Verberne HJ, Burchert W, Knuuti J, Povinec P, Sambuceti G, et al. I-123-mIBG myocardial imaging for assessment of risk for a major cardiac event in heart failure patients: insights from a retrospective European multicenter study. Eur J Nucl Med Mol Imaging 2008;35:535-46.
Flotats A, Carrió I, Agostini D, Le Guludec D, Marcassa C, Schaffers M, et al. Proposal for standardization of 123I-metaiodobenzylguanidine (MIBG) cardiac sympathetic imaging by the EANM Cardiovascular Committee and the European Council of Nuclear Cardiology. Eur J Nucl Med Mol Imaging 2010;37:1802-12.
Petretta M, Pellegrino T, Cuocolo A. The ‘gray zone’ for the heart to mediastinum MIBG uptake ratio. J Nucl Cardiol 2014;21:921-4.
Nakajima K, Okuda K, Matsuo S, Agostini D. The time has come to standardize 123I-MIBG heart-to-mediastinum ratios including planar and SPECT methods. Eur J Nucl Med Mol Imaging 2015;43:386-8.
Nakajima K, Okuda K, Yoshimura M, Matsuo S, Wakabayashi H, Imanishi Y, et al. Multicenter cross-calibration of I-123 metaiodobenzylguanidine heart-to-mediastinum ratios to overcome camera-collimator variations. J Nucl Cardiol 2014;21:970-8.
Matsuo S, Nakajima K, Okuda K, Kawano M, Ishikawa T, Hosoya T, et al. Standardization of the heart-to-mediastinum ratio of 123I-labelled-metaiodobenzylguanidine uptake using the dual energy window method: feasibility of correction with different camera–collimator combinations. Eur J Nucl Med Mol Imaging 2009;36:560-6.
Pellegrino T, Petretta M, De Luca S, Paolillo S, Boemio A, Carotenuto R, et al. Observer reproducibility of results from a low-dose I-123-metaiodobenzylguanidine cardiac imaging protocol in patients with heart failure. Eur J Nucl Med Mol Imaging 2013;40:1549-57.
van der Veen L, Scholte A, Stokkel M. Mathematical methods to determine quantitative parameters of myocardial 123I-MIBG studies: A review of the literature. Nucl Med Commun 2010;31:617-28.
Somsen GA, Verberne HJ, Fleury E, Righetti A. Normal values and within-subject variability of cardiac I-123 MIBG scintigraphy in healthy individuals: Implications for clinical studies. J Nucl Cardiol 2004;11:126-33.
Veltman CE, Boogers MJ, Meinardi JE, Al Younis I, Dibbets-Schneider P, Van der Wall EE, et al. Reproducibility of planar I-123-meta-iodobenzylguanidine (MIBG) myocardial scintigraphy in patients with heart failure. Eur J Nucl Med Mol Imaging 2012;39:1599-608.
Jacobson AF, Matsuoka DT. Influence of myocardial region of interest definition on quantitative analysis of planar I-123-mIBG images. Eur J Nucl Med Mol Imaging 2013;40:558-64.
Slomka PJ, Mehta PK, Germano G, Berman DS. Quantification of I-123-meta-iodobenzylguanidine heart-to-mediastinum ratios: Not so simple after all. J Nucl Cardiol 2014;21:979-83.
Okuda K, Nakajima K, Hosoya T, Ishikawa T, Konishi T, Matsubara K, et al. Semi-automated algorithm for calculating heart-to-mediastinum ratio in cardiac Iodine-123 MIBG imaging. J Nucl Cardiol 2011;18:82-9.
Bland JM, Altman DG. Statistical methods for assessing agreement between two methods of clinical measurement. Lancet 1986;327:307-10.
Sardanelli F, Di Leo G. Biostatistics for radiologists. Milan: Springer; 2009. p. 133-4.
Bland JM, Altman DG. Measuring agreement in method comparison studies. Stat Methods Med Res 1999;8:135-60.
Iskandrian AE, Hage FG, Shaw LJ, Mahmarian JJ, Berman DS. Serial myocardial perfusion imaging defining a significant change and targeting management decisions. JACC 2014;7:79-96.
Kasama S, Toyama T, Sumino H, Nakazawa M, Matsumoto N, Sato Y, et al. Prognostic value of serial cardiac I-123-MIBG Imaging in patients with stabilized chronic heart failure and reduced left ventricular ejection fraction. J Nucl Med 2008;49:907-14.
Drakos SG, Athanasoulis T, Malliaras KG, Terrovitis JV, Diakos N, Koudoumas D, et al. Myocardial sympathetic innervation and long-term left ventricular mechanical unloading. JACC 2010;3:64-70.
Matsui T, Tsutamoto T, Maeda K, Kusukawa J, Kinoshita M. Prognostic value of repeated 123I-metaiodobenzylguanidine imaging in patients with dilated cardiomyopathy with congestive heart failure before and after optimized treatments-comparison with neurohumoral factors. Circulation 2002;66:537-43.
Nakajima K, Nakata T, Yamada T, Yamashina S, Momose M, Kasama S, et al. A prediction model for 5-year cardiac mortality in patients with chronic heart failure using I-123-metaiodobenzylguanidine imaging. Eur J Nucl Med Mol Imaging 2014;41:1673-82.
Nakajima K, Matsumoto N, Kasai T, Matsuo S, Kiso K, Okuda K. Normal values and standardization of parameters in nuclear cardiology: Japanese Society of Nuclear Medicine working group database. Ann Nucl Med. 2016;30:188-99.
Verschure DO, Bongers V, Hagen PJ, Somsen GA, van Eck-Smit BLF, Verberne HJ. Impact of a predefined mediastinal ROI on inter-observer variability of planar I-123-MIBG heart-to-mediastinum ratio. J Nucl Cardiol 2014;21:605-13.
Sardanelli F, Di Leo G. Biostatistics for radiologists. Milan: Springer; 2009. p. 128.
Disclosure
KN has a collaborative research work for creating ROI setting software in this study with FUJIFILM RI Pharma, Co. Ltd, Tokyo, Japan. CM received support from the German Centre for Cardiovascular Research (DZHK) (grant number 81Z4710141) and from the Förderverein des Universitären Herzzentrums Hamburg e.V. The other authors have no conflict of interest to disclose.
Author information
Authors and Affiliations
Corresponding author
Additional information
Christiane Klene and Christiane Jungen have contributed equally.
All editorial decisions for this article, including selection of reviewers and the final decision, were made by guest editor Nagara Tamaki, MD.
Rights and permissions
About this article
Cite this article
Klene, C., Jungen, C., Okuda, K. et al. Influence of ROI definition on the heart-to-mediastinum ratio in planar 123I-MIBG imaging. J. Nucl. Cardiol. 25, 208–216 (2018). https://doi.org/10.1007/s12350-016-0708-8
Received:
Accepted:
Published:
Issue Date:
DOI: https://doi.org/10.1007/s12350-016-0708-8